Tweedie Calculus2


Abstract

Tweedie’s formula, which under Gaussian noise expresses the posterior mean of a latent variable directly from the observed-data density, is a cornerstone of empirical Bayes and measurement-error analysis. No general theory, however, explains when analogous identities hold, how they are structured, or how to derive them for non-Gaussian noise and for posterior functionals other than the mean. This paper develops such a framework for additive-noise models. I characterize when conditional expectations of an unobserved latent variable, given the observed signal, admit direct expressions in terms of the observed density—identities I call Tweedie representations—and show that they are governed by a linear map, the Tweedie functional. Under general conditions, I prove that this functional exists, is unique, and is continuous. I provide a constructive method for its computation based on Fourier analysis: the functional is obtained by extending the inverse Fourier transform of an explicit tempered distribution. The theory yields posterior-mean formulas for non-Gaussian noise and provides new representations for nonlinear posterior functionals. Applications include Laplace mechanisms in differential privacy and heteroskedastic Gaussian sequence models in compound decision problems.

MSC classification: Primary 62C12; Secondary 62C25, 62Q05, 46F10.

Keywords: Tweedie’s formula; empirical Bayes; deconvolution; tempered distributions.

0.0.1 Introduction↩︎

Many statistical problems are naturally formulated in terms of latent effects observed through noise. In compound decision, measurement error, and empirical Bayes problems, estimands such as posterior means depend not only on the noise model but also on the unknown distribution of those latent effects. This naturally shifts attention to recovering that distribution from the data, a task known as deconvolution. Deconvolution, however, is notoriously difficult: it is an ill-posed inverse problem, and the object to be recovered is itself infinite-dimensional.

Tweedie’s formula shows that one can estimate posterior means without recovering the latent distribution. Suppose that \(Y \sim \mathcal{N}(X, \sigma^2)\), where \(X \sim P_X\) is an unknown latent signal. [1] credits Maurice Tweedie with the identity \[\label{Eq:32Tweedie} \mathbb{E}[X \mid Y = y] = y + \sigma^2 \frac{f_Y'(y)}{f_Y(y)},\tag{1}\] where \(f_Y\) is the marginal density of the observable \(Y\). The identity represents the posterior mean directly in terms of the observable density, which can be estimated without recovering the latent distribution \(P_X\).

Accordingly, Tweedie’s formula provides a route to estimation and inference that avoids direct estimation of the latent signal distribution. Rather than estimate the latent law, one can express posterior functionals as transformations of the observed marginal density and then estimate that marginal density from the data.3 This perspective is useful beyond computation. For the posterior mean, Tweedie’s formula gives a shrinkage interpretation: the posterior mean equals the observation plus a correction determined by the observed marginal density. In the Gaussian location model, this correction moves \(y\) toward regions of higher observed density, with magnitude governed by the noise variance and the score \(f_Y'(y)/f_Y(y)\).4 In some models, Tweedie-type representations also imply shape restrictions, such as monotonicity, that can improve estimation [6]. They also identify the source of statistical difficulty. In the Gaussian posterior-mean case, estimation reduces to estimating pointwise derivatives of the observed marginal density, which has polynomial minimax rates under standard smoothness conditions [7], [8]. This contrasts with full nonparametric recovery of the latent law, which can have only logarithmic minimax rates under Gaussian noise [9].

Although formulas of this form are available for particular models and particular estimands, there is no general framework that explains when they exist, what structure they share, or how they can be derived. This paper provides such a framework. I consider general additive-noise models: triples of \(\mathbb{R}^d\)-valued random variables \((Y,X,V)\) satisfying \(Y=X+V\) with \(X\perp\!\!\!\!\perp V\). For a broad class of functions \(g\) and noise laws \(V\), I study when posterior expectations5 admit a representation of the form \[\label{Eq:32TweedieRep} \theta_V^g(y)=\mathbb{E}[g(X)\mid Y=y] = \frac{\mathcal{T}_{g,V,y}[f_Y]}{f_Y(y)},\tag{2}\] where \(\mathcal{T}_{g,V,y}\) is a linear functional on a function space containing all possible observed densities. It depends on the estimand \(g\), the noise law of \(V\), and the evaluation point \(y\), but not on the latent distribution \(P_X\). For example, in the one-dimensional Gaussian case with \(g(x)=x\), the functional in question is \[\mathcal{T}_{g,V,y}[f_Y] = y f_Y(y) + \sigma^2 f_Y'(y),\] which recovers 1 . I call \(\mathcal{T}_{g,V,y}\) the Tweedie functional, and I call any expression of the form 2 a Tweedie representation. I characterize when such functionals exist and provide a general strategy to compute them in closed form.

Several functionals fit into this notation. The examples below are common in the literature and will be used throughout the paper.

  • Posterior moments. For a scalar latent variable, posterior moments correspond to polynomial choices of \(g\). The most used is the posterior mean, which is the Bayes rule for estimating the latent variable under squared-error loss. The conditional risk of this rule is the posterior variance. Since the posterior variance is determined by the first two posterior moments, it can also be expressed as a function of the marginal density of the data. More generally, posterior risks under polynomial loss functions can be written in terms of finitely many posterior moments, so they can likewise be expressed through the observed marginal density.

  • Posterior cumulative distribution function. For \(t\in\mathbb{R}\), the posterior cumulative distribution function corresponds to the indicator \(g_t(x)=\mathbb{1}\{x\le t\}\). Thus \(F_{X\mid Y}(t\mid y)=\mathbb{E}[\mathbb{1}\{X\le t\}\mid Y=y]\). This functional encompasses several quantities of interest. In large-scale studies, a common target is the posterior probability that an effect is positive, \(\Pr(X>0\mid Y=y)=1-F_{X\mid Y}(0\mid y)\). Such sign probabilities arise when assessing directional evidence across many units and have been studied in both theoretical and applied work; see [5], [10][13]. A related quantity is the local false sign rate [14], \(\min\{\text{Pr}(X \leq 0 \mid Y=y),\text{Pr}(X \geq 0 \mid Y=y)\}\), the posterior probability of a sign error when reporting the more probable sign.

  • Posterior moment generating function. For \(t\in\mathbb{R}^d\), the posterior moment generating function corresponds to \(g_t(x)=\exp(t^\top x)\). When finite in a neighborhood of zero, the posterior moment generating function characterizes the posterior distribution and can be used to recover posterior moments and other distributional features. Moment generating functions also provide a standard tool for deriving tail bounds; see [15], Chapter 2.

The preceding examples motivate three questions about Tweedie representations that organize the paper:

  1. Existence and regularity of the Tweedie functional. Section 0.0.3 asks when a posterior functional admits a Tweedie representation of the form 2 . The main result, Theorem 1, gives sufficient conditions under which the Tweedie functional exists, is unique, and is continuous in a particular topology. The theorem applies to a broad class of additive-noise models, including cases where the law of \(V\) need not be symmetric or have full support. Although the result is not constructive, it gives a general structural characterization of such representations.

  2. Strategy for computing Tweedie representations. Section 0.0.4 builds on the existence result and develops a general method for deriving Tweedie representations through Fourier analysis. The main tool is the theory of tempered distributions, developed by [16] and reviewed in Section 0.0.2. This language is needed because the relevant inverse Fourier transforms need not exist as ordinary functions. More importantly, it also provides a Fourier theory for linear functionals: with it, Fourier inversion applies not only to functions, but also to linear maps, delivering a calculus for functionals.

    The main result, Theorem 2, shows that, under suitable conditions, the Tweedie functional can be computed from the inverse Fourier transform of a known, computable linear functional. A major practical advantage of this viewpoint is that it reduces the derivation of Tweedie representations to the computation of inverse Fourier transforms. In this sense, the problem becomes one of calculus. As such, the relevant inverse transform can be computed directly or identified from standard transform tables, much as Laplace-transform tables are used in the study of differential equations. Useful references for this purpose include [17] and the Appendix of [18].

  3. Applications. Section 0.0.5 illustrates the scope of the framework through several applications. First, it uses the Fourier-based strategy of Section 0.0.4 to derive posterior-mean representations for a broad class of noise distributions. Table [tab:noise-families] summarizes these formulas. Except for the Gaussian and Laplace cases, these representations appear to be new.

    Second, Section 0.0.5.3 applies the framework to the conventional Laplace mechanism from differential privacy. The paper derives Tweedie representations for several posterior functionals under this noise structure. Table [tab:laplace-tweedie-functionals] summarizes selected cases.

    Section 0.0.5.4 studies the heteroskedastic Gaussian sequence model. This model is especially important in economics and the social sciences, where researchers often observe noisy estimates of means or effects across many units or populations.6 The Gaussian specification formalizes the normal approximation already implicit in many standard inference procedures, often justified by large-sample central limit arguments. In this model, \(Y\) is a noisy estimate of a latent parameter \(X\), and the noise covariance matrix \(\Sigma\) may vary across units. It may also be random and correlated with \(X\). The key observation is that, after conditioning on \(\Sigma=\Sigma_0\) and standardizing, the model reduces to an additive Gaussian model with fixed covariance. The general framework therefore applies conditionally on \(\Sigma\), yielding Tweedie representations in terms of the conditional density \(f_{Y\mid\Sigma}(\cdot\mid\Sigma_0)\). This conditional formulation gives explicit representations for posterior means and for other empirical Bayes functionals, including posterior covariances, moments, risk functions, distribution functions, and moment generating functions.

0.0.1.1 Relation to the literature.

The paper by [20] is closest to my approach. They show that, for several additive-noise models, the posterior mean can be written as the ratio of a linear operator applied to the observed marginal density and the density itself. They further note that, once such an operator is available, iterating it recovers posterior moments and, more generally, posterior expectations of polynomial functions. This paper formalizes and extends that observation. Rather than build outward from the posterior-mean case, I study when, for a general measurable function \(g\), the conditional expectation \(\mathbb{E}[g(X)\mid Y=y]\) admits an analogous representation. I also establish formal properties of the representing map, including existence, uniqueness, and continuity under the relevant topology. The framework also extends beyond the basic additive-noise setting, for example to heteroskedastic Gaussian sequence models, where the additive-noise structure holds only conditionally.

On the computational side, the paper’s main innovation is to introduce tempered distributions as a tool for deriving Tweedie representations. This serves two purposes. First, it makes rigorous the Fourier calculations that underlie many Tweedie-type identities for posterior moments, including cases in which the relevant inverse Fourier transforms exist only as distributions. Second, it yields a systematic procedure for deriving Tweedie representations for posterior functionals beyond moments, including nonsmooth and non-polynomial targets. Closest in this respect is [21], which uses tempered distributions to derive unbiased estimators under Laplace noise. This approach complements derivations based on Stein identities and exponential-family integration by parts. For example, in exponential families, [22] observes that posterior-moment representations can be obtained by differentiating the log ratio of the marginal density to the base-measure density defining the family. Related identities, including Stein’s lemma and Stein’s unbiased risk estimate, are often derived by integration by parts [23].

The paper also provides several new Tweedie representations. For instance, it derives a Tweedie representation for the posterior cumulative distribution function under Gaussian noise. It also derives analogous representations for posterior means under several non-Gaussian noises, including Cauchy, Gumbel, and Gamma noise. In this respect, the paper is related to the literature on deriving new Tweedie-type identities in Bayesian, empirical Bayes, and measurement-error problems. Historically, the Gaussian identity appears in print in [24], where Dyson attributes it to Arthur Eddington. Later, [1] reported the formula and credited Maurice Kenneth Tweedie. Much of the subsequent literature develops model-specific analogues or extensions of this identity. [25] derives a scale-parameter analogue of Tweedie’s formula for models with known location and unknown scale. [26] and [27] derive exact relationships for posterior moments and cumulants in normal-location and exponential-family settings. [28] obtains an exact representation of the posterior mean for location models with normal scale-mixture priors, and [29] gives a Gaussian linear-regression analogue. [30] derives a chi-square analogue in the empirical Bayes problem of estimating many variances. [31] and [32] develop Laplace-noise-based Tweedie-type formulae for the posterior mean and for polynomial functionals, respectively.

Finally, the paper relates to applications of Tweedie’s formula. These methods are widely used in empirical Bayes problems [2], [22], including large-scale hypothesis testing [33]. More recently, Tweedie formulas have been used in diffusion-based sampling and score-based generative modeling [34][37]. Related denoising problems also arise in differential privacy, where Gaussian or Laplace noise is often added to statistics to limit the information revealed about any single data point. For Laplace noise, [38] propose a correction based on the Tweedie representer for nonlinear method-of-moments models with measurement error, and [39] apply Laplace-based Tweedie-type formulas to measurement-error and regression problems. Tweedie’s formula has also been used for forecasting in dynamic panel models [40]. Recent work by [41], [42] uses identities closely related to Tweedie’s formula to construct shrinkage maps for recovering the latent signal distribution. More broadly, the framework is connected to the deconvolution literature [9], [43][45] and to additive measurement-error models [46][50].

0.0.2 Setup and basic notions in Fourier Analysis↩︎

This section introduces the additive-noise model studied throughout the paper, states the standing assumptions under which the theory is developed, and records several immediate consequences. The framework is intentionally broad: it nests the classical Gaussian model underlying Tweedie’s formula and accommodates more general deconvolution problems in arbitrary dimensions.

0.0.2.1 Setup

Let \(\mathcal{P}(\mathbb{R}^d)\) denote the set of probability measures on \((\mathbb{R}^d,\mathcal{B}(\mathbb{R}^d))\), where \(\mathcal{B}(\mathbb{R}^d)\) is the Borel \(\sigma\)-algebra on \(\mathbb{R}^d\). For a random vector \(Z\), let \(P_Z\) denote its law. Consider a triple of \(d-\)dimensional random vectors \((Y,X,V)\) defined on the same probability space \((\Omega,\mathscr{A}, \mathbb{P})\). Here \(Y \sim P_Y\) is the observed vector, \(X \sim P_X\) is the latent signal of interest, and \(V \sim P_V\) is the noise.

For any \(P \in \mathcal{P}(\mathbb{R}^d)\), let \(\varphi_P : \mathbb{R}^d \to \mathbb{C}\) denote its characteristic function, defined by \[\varphi_P(\omega) \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} e^{i\omega^\top x}\,dP(x) = \mathbb{E}_{Z\sim P}\!\left[e^{i\omega^\top Z}\right], \qquad \omega \in \mathbb{R}^d.\] When \(Z \sim P_Z\), I use the shorthand notation \(\varphi_{Z} \mathrel{\mathop{:}}=\varphi_{P_Z}\). I now state the main assumptions used throughout the paper.

Assumption 1 (Additivity and independence). The triple \((Y,X,V)\) is related by addition \(Y=X+V\), and \(X\) and \(V\) are independent.

Under this assumption, the observed characteristic function factors as \(\varphi_Y(\omega)=\varphi_X(\omega)\varphi_V(\omega)\) for all \(\omega\in\mathbb{R}^d\).7 This factorization is what makes closed-form Tweedie representations possible: it allows terms involving the unknown latent law \(P_X\), encoded by \(\varphi_X\), to be rewritten in terms of the observed marginal law and the known noise law, characterized by \(\varphi_Y\) and \(\varphi_V\).

Assumption 2 (Identification). The noise characteristic function is nonzero almost everywhere: \[\varphi_V(\omega)\neq 0 \quad\text{for Lebesgue-a.e. }\omega\in\mathbb{R}^d.\]

Assumption 2 is the basic nondegeneracy condition behind Fourier deconvolution. Informally, recovering \(P_X\) from the relation \(\varphi_Y(\omega)=\varphi_X(\omega)\varphi_V(\omega)\) requires division by \(\varphi_V(\omega)\). Therefore, this assumption rules out, except on a null set, frequency regions at which inversion breaks down. It is satisfied by the standard Gaussian, Laplace, logistic, and many other common noise laws. It also holds, for example, when \(V\) has compact support.8

Assumption 3 (Noise regularity). The noise distribution \(P_V\) admits a Lebesgue density \(f_V\).

ssumption 3, together with the convolution structure imposed by Assumption 1, has two immediate consequences. First, the observed law \(P_Y\) is absolutely continuous with respect to Lebesgue measure, so the observed density \(f_Y\) appearing in Tweedie representations is well defined. Second, Proposition 1 shows that one version of its density is obtained by convolving the latent law \(P_X\) with the fixed version of the noise density \(f_V\) in Assumption 3. Throughout the paper, \(f_Y\) denotes this convolution version. This convolution formula will be essential for characterizing the Tweedie functional.

Proposition 1. Under assumptions 1 and 3, the law \(P_Y\) is absolutely continuous with respect to Lebesgue measure. A version of its density is \[f_Y(y)=\int_{\mathbb{R}^d} f_V(y-x)\,dP_X(x), \qquad y\in\mathbb{R}^d.\]

0.0.2.2 Some important notions in Fourier analysis

This subsection fixes the Fourier analysis conventions used throughout the paper. It first defines the ordinary Fourier transform for integrable functions and then extends the transform to tempered distributions.

For \(1\le p\le\infty\) and \(\mathbb{K}\in\{\mathbb{R},\mathbb{C}\}\), let \(L^p(\mathbb{R}^d;\mathbb{K})\) denote the usual Lebesgue space, with norm \[\|f\|_p = \begin{cases} \left(\displaystyle\int_{\mathbb{R}^d}|f(x)|^p\,dx\right)^{1/p}, & 1\le p<\infty,\\[1ex] \operatorname*{ess\,sup} \limits_{x\in\mathbb{R}^d}|f(x)|, & p=\infty. \end{cases}\] When \(\mathbb{K}\) is omitted, it is understood to be \(\mathbb{R}\). The symbol \(i\) denotes the imaginary unit, and \(\overline{z}\) denotes the complex conjugate of \(z\in\mathbb{C}\). Let \(C_0(\mathbb{R}^d;\mathbb{K})\) denote the space of continuous \(\mathbb{K}\)-valued functions on \(\mathbb{R}^d\) that vanish at infinity.

For \(\psi\in L^1(\mathbb{R}^d;\mathbb{C})\), define its Fourier transform by \[\widetilde{\psi}(\omega) \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} e^{i\omega^\top x}\psi(x)\,dx, \qquad \omega\in\mathbb{R}^d.\] For \(\psi\in L^1(\mathbb{R}^d;\mathbb{C})\), let \(\psi^\sharp\) denote the inverse Fourier integral \[\psi^\sharp(x) \mathrel{\mathop{:}}= \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} e^{-i\omega^\top x}\psi(\omega)\,d\omega, \qquad x\in\mathbb{R}^d,\] whenever this integral is well defined. Thus \(\psi\mapsto\psi^\sharp\) denotes the inverse Fourier operation under the convention above. If \(\psi,\widetilde{\psi}\in L^1(\mathbb{R}^d;\mathbb{C})\), Fourier inversion gives \[\psi(x) = \widetilde{\psi}^\sharp(x) = \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} e^{-i\omega^\top x}\widetilde{\psi}(\omega)\,d\omega\] for Lebesgue-a.e. \(x\in\mathbb{R}^d\).

For the present paper, this classical framework is too narrow. Many objects that arise in the computation of Tweedie representations are not integrable, so their inverse Fourier transforms need not exist as functions. More importantly, Tweedie functionals are linear maps acting on the observed density. Consequently, it is advantageous to use a Fourier theory that can transform and invert linear functionals, rather than one limited to ordinary functions. I use the framework of tempered distributions, introduced by [16], for this purpose. This framework extends Fourier analysis from functions to continuous linear functionals and thus provides a natural language for deconvolution problems.

The starting point is the Schwartz space on \(\mathbb{R}^d\), denoted by \(\mathscr S(\mathbb{R}^d)\). It is the space of smooth test functions against which tempered distributions will be evaluated. Formally, \[\mathscr{S}(\mathbb{R}^d) \mathrel{\mathop{:}}= \left\{ \psi\in C^\infty(\mathbb{R}^d;\mathbb{C}) : \sup_{x\in\mathbb{R}^d} \bigl|x^{\alpha} \partial^{\beta} \psi(x)\bigr|<\infty \text{ for all multi-indices }\alpha,\beta\in\mathbb{N}_0^d \right\}.\] Here \(x^{\alpha} \mathrel{\mathop{:}}=x_1^{\alpha_1}\cdots x_d^{\alpha_d}\), \(\partial^{\beta} \mathrel{\mathop{:}}=\partial^{|\beta|}/ \partial x_1^{\beta_1}\cdots \partial x_d^{\beta_d}\), and \(|\beta|=\beta_1+\cdots+\beta_d\). Thus \(\mathscr S(\mathbb{R}^d)\) consists of smooth functions whose derivatives decay faster than any inverse polynomial. It contains, for example, compactly supported smooth functions and Gaussian densities.

The Fourier transform is especially well behaved on \(\mathscr S(\mathbb{R}^d)\). The map \(\psi\mapsto\widetilde{\psi}\) is a continuous automorphism of \(\mathscr S(\mathbb{R}^d)\), with inverse \(\psi\mapsto\psi^\sharp\). Thus every Schwartz function has a Fourier transform, and every Schwartz function is the inverse Fourier transform of another Schwartz function. Continuity is understood with respect to the standard Schwartz topology, under which \(\mathscr S(\mathbb{R}^d)\) is a Fréchet space.9 Appendix 1.0.1.1 provides additional details on this construction.

A tempered distribution is a continuous linear functional on \(\mathscr S(\mathbb{R}^d)\). I write \(\mathscr S'(\mathbb{R}^d) \mathrel{\mathop{:}}= \bigl(\mathscr S(\mathbb{R}^d)\bigr)'\) for the space of tempered distributions. Critically, many ordinary functions define tempered distributions when their integration functionals are continuous on \(\mathscr S(\mathbb{R}^d)\). Specifically, if \(Q:\mathbb{R}^d\to\mathbb{C}\) is measurable and \[\mathcal{I}_Q[\psi] \mathrel{\mathop{:}}= \int_{\mathbb{R}^d}Q(x)\psi(x)\,dx, \qquad \psi\in\mathscr S(\mathbb{R}^d),\] defines a continuous linear functional on \(\mathscr S(\mathbb{R}^d)\), then \(\mathcal{I}_Q\in\mathscr S'(\mathbb{R}^d)\).10 The space \(\mathscr S'(\mathbb{R}^d)\) also contains singular distributions that are not induced by ordinary functions. For example, evaluation at a point \(a\in\mathbb{R}^d\), \[\operatorname{ev}_a[\psi]\mathrel{\mathop{:}}=\psi(a), \qquad \psi\in\mathscr S(\mathbb{R}^d),\] is a tempered distribution.

The Fourier transform extends from Schwartz functions to tempered distributions by duality. With the convention above, define operators \(\mathcal{F},\mathcal{F}^{-1}:\mathscr S'(\mathbb{R}^d)\to \mathscr S'(\mathbb{R}^d)\) by \[\mathcal{F}\{T\}[\psi] \mathrel{\mathop{:}}= T[\widetilde{\psi}], \qquad \mathcal{F}^{-1}\{T\}[\psi] \mathrel{\mathop{:}}= T[\psi^\sharp], \qquad \psi\in\mathscr S(\mathbb{R}^d).\] These definitions are well posed because the maps \(\psi\mapsto\widetilde{\psi}\) and \(\psi\mapsto\psi^\sharp\) map \(\mathscr S(\mathbb{R}^d)\) continuously to itself. Under the weak-\(\star\) topology on \(\mathscr S'(\mathbb{R}^d)\), the operators \(\mathcal{F}\) and \(\mathcal{F}^{-1}\) are continuous automorphisms; see Appendix 1.0.1.1.

0.0.3 Existence of the Tweedie functional↩︎

This section develops the existence theory for Tweedie representations. In the additive-noise model, the problem reduces to the convolution operator induced by the noise. I characterize when this operator is invertible on its range and use the resulting inverse to equip the class of admissible observed densities with a natural topology.

To formalize the representation problem, let \(\lambda:\mathbb{R}^d\to\mathbb{C}\) be measurable and define \[\Lambda_\lambda(P_X) \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} \lambda(x)\,dP_X(x),\] whenever the integral is well defined. The question is whether this latent functional depends on \(P_X\) only through the observed marginal density \(f_Y\). Given a triple \((Y,X,V)\) satisfying Assumptions 13, I identify a class of integrands \(\lambda\) for which there exists a unique linear functional \(\mathcal{T}_{\lambda,V}\) satisfying \(\Lambda_\lambda(P_X)=\mathcal{T}_{\lambda,V}[f_Y]\). For these integrands, the latent integral is therefore representable in terms of the observed density alone.

To state this result, let \(\mathcal{M}(\mathbb{R}^d)\) denote the space of finite complex Borel measures on \(\mathbb{R}^d\). For \(\mu\in\mathcal{M}(\mathbb{R}^d)\), define its total variation norm by \[\|\mu\|_{TV} \mathrel{\mathop{:}}= \sup\left\{ \left|\int_{\mathbb{R}^d} h(x)\,d\mu(x)\right| : h\in C_0(\mathbb{R}^d;\mathbb{C}),\;\|h\|_\infty\le 1 \right\}.\] It is well known that \(\bigl(\mathcal{M}(\mathbb{R}^d),\|\cdot\|_{TV}\bigr)\) is a complex Banach space [54]. Since \(\mathcal{P}(\mathbb{R}^d)\subseteq \mathcal{M}(\mathbb{R}^d)\), the results below apply in particular to probability measures. I nevertheless work on \(\mathcal{M}(\mathbb{R}^d)\) because its vector space structure will be useful throughout.

Given the noise law \(P_V\) with density \(f_V\), define the convolution operator \(\mathcal{K}_V:\mathcal{M}(\mathbb{R}^d)\to L^1(\mathbb{R}^d;\mathbb{C})\) by \[\mathcal{K}_V[\mu](y) \mathrel{\mathop{:}}= (f_V * \mu)(y) = \int_{\mathbb{R}^d} f_V(y-x)\,d\mu(x), \qquad y\in\mathbb{R}^d.\] The operator \(\mathcal{K}_V\) is linear and continuous from \(\bigl(\mathcal{M}(\mathbb{R}^d),\|\cdot\|_{TV}\bigr)\) into \(\bigl(L^1(\mathbb{R}^d;\mathbb{C}),\|\cdot\|_1\bigr)\). Indeed, it is immediate from the definition that \(\|\mathcal{K}_V[\mu]\|_1 \le \|\mu\|_{TV}\).

The range of \(\mathcal{K}_V\) consists of all \(L^1\) functions obtainable by convolving the noise density \(f_V\) against a finite complex Borel measure. I call this range the class of \(V\)-admissible mixtures and write \[\mathcal{A}_V(\mathbb{R}^d) \mathrel{\mathop{:}}= \{f=\mathcal{K}_V[\mu]=f_V * \mu : \mu\in\mathcal{M}(\mathbb{R}^d)\} \subseteq L^1(\mathbb{R}^d;\mathbb{C}).\] By Proposition 1, whenever the observed density \(f_Y\) exists, it belongs to \(\mathcal{A}_V(\mathbb{R}^d)\).

I next establish that \(\mathcal{K}_V\) is a bijection between latent measures and \(V\)-admissible mixtures. Surjectivity is immediate from the definition of \(\mathcal{A}_V(\mathbb{R}^d)\). The remaining issue is injectivity. Assumption 2 provides it by ruling out distinct latent measures that generate the same mixture.

Proposition 2. Under Assumption 2, the operator \(\mathcal{K}_V\) is a bijection between \(\mathcal{M}(\mathbb{R}^d)\) and \(\mathcal{A}_V(\mathbb{R}^d)\).

Proposition 2 implies the inverse \(\mathcal{K}_V^{-1} : \mathcal{A}_V(\mathbb{R}^d) \to \mathcal{M}(\mathbb{R}^d)\) is well defined. I use this inverse to transfer the total variation norm from \(\mathcal{M}(\mathbb{R}^d)\) to \(\mathcal{A}_V(\mathbb{R}^d)\). Specifically, if \(f \in \mathcal{A}_V(\mathbb{R}^d)\) and \(f = f_V \ast \mu\) for some \(\mu \in \mathcal{M}(\mathbb{R}^d)\), define \[\|f\|_{\mathcal{A}_V} \mathrel{\mathop{:}}= \|\mathcal{K}_V^{-1}[f]\|_{TV} = \|\mu\|_{TV}.\]

This definition is unambiguous because Proposition 2 gives a unique representing measure \(\mu\). Furthermore, with this norm, \(\mathcal{K}_V : \bigl(\mathcal{M}(\mathbb{R}^d),\|\cdot\|_{TV}\bigr) \to \bigl(\mathcal{A}_V(\mathbb{R}^d),\|\cdot\|_{\mathcal{A}_V}\bigr)\) is an isometric isomorphism. Hence \(\mathcal{A}_V(\mathbb{R}^d)\) inherits the Banach space structure of \(\mathcal{M}(\mathbb{R}^d)\). Let \(\mathcal{A}_V'(\mathbb{R}^d) \mathrel{\mathop{:}}= \bigl(\mathcal{A}_V(\mathbb{R}^d)\bigr)'\) denote the Banach dual of \(\mathcal{A}_V(\mathbb{R}^d)\), that is, the space of continuous linear functionals on \(\mathcal{A}_V(\mathbb{R}^d)\). The next theorem shows that the density-based representation maps sought here are precisely elements of this dual space.

Theorem 1 (Existence and uniqueness of the representing functional). Let \((Y,X,V)\) satisfy Assumptions 2 and 3. For every \(\lambda\in C_0(\mathbb{R}^d;\mathbb{C})\), there exists a unique functional \(\mathcal{T}_{\lambda,V}\in \mathcal{A}'_V(\mathbb{R}^d)\) such that \[\mathcal{T}_{\lambda,V}\!\left[\mathcal{K}_V[\mu]\right] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu(x) \qquad \text{for all }\mu\in\mathcal{M}(\mathbb{R}^d).\] In particular, under Assumption 1, \(f_Y = \mathcal{K}_V[P_X]\), and so \[\mathcal{T}_{\lambda,V}[f_Y] = \int_{\mathbb{R}^d} \lambda(x)\, dP_X(x).\]

Theorem 1 establishes existence and uniqueness of the representation map. Specifically, for any \(\lambda\in C_0(\mathbb{R}^d)\), the theorem gives a unique continuous linear functional \(\mathcal{T}_{\lambda,V}\in \mathcal{A}_V'(\mathbb{R}^d)\) such that \(\mathcal{T}_{\lambda,V}[\mathcal{K}_V[\mu]] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu(x)\) for every \(\mu\in\mathcal{M}(\mathbb{R}^d)\). Applying this identity to the observed density \(f_Y=\mathcal{K}_V[P_X]\) shows that the latent integral \(\Lambda_\lambda(P_X)\) can be recovered as the value of a continuous linear functional of \(f_Y\).

An immediate consequence of Theorem 1 is the existence and uniqueness of the Tweedie representation. The key point is that, after applying Bayes’ formula to \(\theta_V^g\), the numerator is an integral of a known function with respect to the latent law \(P_X\). Indeed, under Assumptions 1 and 3, for any \(y\) with \(f_Y(y)>0\), \[\label{Eq:32ratio} \theta_V^g(y) = \frac{1}{f_Y(y)} \int_{\mathbb{R}^d} \lambda_{g,V,y}(x)\,dP_X(x) = \frac{\Lambda_{\lambda_{g,V,y}}(P_X)}{f_Y(y)}, \quad \lambda_{g,V,y}(x)\mathrel{\mathop{:}}=g(x)f_V(y-x).\tag{3}\]

Thus, whenever \(\lambda_{g,V,y}\in C_0(\mathbb{R}^d)\), the numerator in 3 falls under Theorem 1. This gives the following corollary.

Corollary 1 (Existence and uniqueness of the Tweedie functional). Fix \(y\in\mathbb{R}^d\) and let \(g:\mathbb{R}^d\to\mathbb{R}\) be measurable. Under Assumptions 1, 2, and 3, if \(x \mapsto \lambda_{g,V,y}(x)=g(x)f_V(y-x) \in C_0(\mathbb{R}^d;\mathbb{C})\), then there exists a unique \(\mathcal{T}_{g,V,y}\in\mathcal{A}_V'(\mathbb{R}^d)\) such that \[\mathcal{T}_{g,V,y}\!\left[\mathcal{K}_V[\mu]\right] = \int_{\mathbb{R}^d} g(x)f_V(y-x)\,d\mu(x), \qquad \forall \mu\in\mathcal{M}(\mathbb{R}^d).\] Consequently, if \(X\sim P_X\), \(f_Y=\mathcal{K}_V[P_X]\in\mathcal{A}_V(\mathbb{R}^d)\), and \(f_Y(y)>0\), then the posterior expectation of \(g(X)\) given \(Y=y\) is finite and satisfies \[\theta_V^g(y) = \mathbb{E}[g(X)\mid Y=y] = \frac{\mathcal{T}_{g,V,y}[f_Y]}{f_Y(y)}.\]

Remark 1. The representation is defined only at points \(y\) such that \(f_Y(y)>0\). This restriction is harmless for most statements about \(Y\), since the representation is defined \(P_Y\)-almost surely: \[P_Y(\{y:f_Y(y)=0\}) = \int_{\{y:f_Y(y)=0\}} f_Y(y)\,dy = 0.\]

Remark 2. A limitation of the preceding corollary is that it applies only when the integrand \(\lambda_{g,V,y}\) is continuous and vanishes at infinity. This excludes important cases, such as indicator functions \(g\), which are needed to represent posterior cumulative distribution functions. Section 0.0.4.2 later removes this restriction by showing that the corresponding Tweedie functionals arise as limits of Tweedie functionals associated with continuous approximations to \(g\).

Remark 3. Corollary 1 provides a pointwise identity for each fixed \(y\in\mathbb{R}^d\). In many applications, however, the object of interest is the conditional mean as a function of the observation, namely \(\mathbb{E}[g(X)\mid Y]\) viewed as an integrable \(\sigma(Y)\)-measurable random variable. Proposition 7 in Appendix 1.0.1.4 gives an operator-level version of the pointwise representation. Concretely, it establishes under further regularity that the pointwise maps \(\mathcal{T}_{g,V,y}\) are obtained by evaluating a single linear operator \(\mathscr{T}_{g,V}\): \[\mathscr{T}_{g,V}[f_Y](y) = \mathcal{T}_{g,V,y}[f_Y] \qquad \text{for every } y \text{ with } f_Y(y)>0.\] Consequently, the conditional mean admits the global representation \[\mathbb{E}[g(X)\mid Y] = \frac{\mathscr{T}_{g,V}[f_Y](Y)}{f_Y(Y)} \qquad \mathbb{P}\text{-almost surely}.\] I call \(\mathscr{T}_{g,V}\) the Tweedie operator. This formulation separates the dependence on the observed density from the dependence on the evaluation point: the density \(f_Y\) is first mapped to the function \(\mathscr{T}_{g,V}[f_Y]\), and the pointwise numerator is then obtained by evaluation. Equivalently, it factors the Tweedie functional as \(\mathcal{T}_{g,V,y}=\operatorname{ev}_y \circ \mathscr{T}_{g,V}\) on the common domain where both sides are defined. Because the image of \(\mathscr{T}_{g,V}\) can be characterized, this operator-level representation provides a way to study global regularity properties of the posterior mean. In particular, Corollary 2 uses this structure to establish differentiability of \(\mathbb{E}[g(X)\mid Y]\). A related operator-level formulation for posterior means appears in [20], Eq. 3.5.

0.0.4 Computing Tweedie representations↩︎

For each \(y\in\mathbb{R}^d\), Section 0.0.3 constructed a continuous linear functional \(\mathcal{T}_{g,V,y}\in\mathcal{A}'_V(\mathbb{R}^d)\) such that, under the additive-noise model, whenever \(f_Y(y)>0\), \[\theta_V^g(y) = \frac{1}{f_Y(y)}\,\mathcal{T}_{g,V,y}[f_Y], \quad \mathcal{T}_{g,V,y}[f_Y] = \int_{\mathbb{R}^d}\lambda_{g,V,y}(x)\,dP_X(x), \quad \mathcal{T}_{g,V,y}\in\mathcal{A}'_V(\mathbb{R}^d).\] To carry out this strategy, however, I need to impose additional regularity on the noise density. This regularity is inherited by \(V\)-mixtures: if the noise density has \(k\) continuous derivatives that vanish at infinity, then every mixture generated by this noise has the same degree of smoothness. This assumption seems natural in the present problem. Indeed, in the Gaussian case, Tweedie’s formula already requires differentiability of the observed marginal density.

The smoothness assumption lets us work in an ambient Banach space whose topology is weaker than the original \(\mathcal{A}_V\)-topology used for existence. Crucially, Schwartz functions are dense in this weaker topology. Since the Schwartz space is the natural setting for Fourier inversion of tempered distributions, we can perform the deconvolution and inverse Fourier calculation there, and then extend the resulting functional continuously to all \(V\)-mixtures. This is how the abstract functional from Section 0.0.3 becomes computable.

I now make this construction explicit. For \(k\in\mathbb{N}_0\), define \[C_0^k(\mathbb{R}^d;\mathbb{C}) \mathrel{\mathop{:}}= \left\{ \psi\in C^k(\mathbb{R}^d;\mathbb{C}) : \partial^\alpha \psi\in C_0(\mathbb{R}^d;\mathbb{C}) \text{ for all } |\alpha|\le k \right\},\] Thus \(C_0^k(\mathbb{R}^d;\mathbb{C})\) is the space of \(k\)-times continuously differentiable functions whose derivatives up to order \(k\) vanish at infinity. Now define \[\Xi^k(\mathbb{R}^d;\mathbb{C}) \mathrel{\mathop{:}}= C_0^k(\mathbb{R}^d;\mathbb{C})\cap L^1(\mathbb{R}^d;\mathbb{C}), \qquad \|\psi\|_{\Xi^k} \mathrel{\mathop{:}}= \max_{|\alpha|\le k}\|\partial^\alpha \psi\|_\infty+\|\psi\|_1.\]

Assumption 4 (Noise smoothness of order \(k\)). For some \(k\in\mathbb{N}_0\), the noise density \(f_V\) belongs to \(C_0^k(\mathbb{R}^d;\mathbb{R})\).

Assumption 4 says that the noise density has continuous derivatives up to order \(k\), all of which vanish at infinity. Since \(f_V\) is a density, the assumption naturally implies that \(f_V\in\Xi^k(\mathbb{R}^d;\mathbb{C})\). This assumption encompasses many common noise laws, for suitable choices of \(k \geq 0\), such as Gaussian, logistic, Gumbel, Laplace, and Cauchy distributions.

The next lemma records the basic facts about this space used to establish the main theorem. The space \(\Xi^k\) is a Banach space; the space of \(V\)-mixtures embeds continuously into \(\Xi^k\); and Schwartz functions are dense in \(\Xi^k\).

Lemma 1 (Mixture smoothness and approximation). Assume \(f_V\) satisfies Assumption 4 with smoothness order \(k\). Then:

  • Completeness. \((\Xi^k(\mathbb{R}^d;\mathbb{C}),\|\cdot\|_{\Xi^k})\) is a Banach space.

  • \(V\)-mixtures inherit noise regularity. The inclusion \(\mathcal{A}_V(\mathbb{R}^d)\hookrightarrow \Xi^k(\mathbb{R}^d;\mathbb{C})\) is continuous.

  • Schwartz approximation. The inclusion \(\mathscr S(\mathbb{R}^d)\hookrightarrow \Xi^k(\mathbb{R}^d;\mathbb{C})\) is continuous, and \(\mathscr S(\mathbb{R}^d)\) is dense in \((\Xi^k(\mathbb{R}^d;\mathbb{C}),\|\cdot\|_{\Xi^k})\).

0.0.4.1 A general strategy for computing Tweedie representations

I now state the main result of this section, and the main computational result of the paper.

Theorem 2 (Computation of Tweedie functionals). Fix \(y\in\mathbb{R}^d\) and let \(g:\mathbb{R}^d\to\mathbb{R}\) be measurable. Suppose that \(V\) satisfies Assumptions 2 and 4 for some \(k\ge 0\). Let \(x \mapsto g(x)f_V(y-x) \eqqcolon\lambda_{g,V,y}(x)\in C_0(\mathbb{R}^d;\mathbb{C})\). Suppose there exists a measurable function \(\mathcal{Q}_{g,V,y}:\mathbb{R}^d \to \mathbb{C}\) such that

  1. Temperedness. There exists \(N\in\mathbb{N}_0\) such that \[\int_{\mathbb{R}^d} \frac{|\mathcal{Q}_{g,V,y}(\omega)|}{(1+\|\omega\|_2)^N}\,d\omega <\infty.\]

  2. \(\Xi^k\)-continuity. There exists \(C>0\) such that, for every \(\psi\in\mathscr S(\mathbb{R}^d)\), \[\bigl|\mathcal{F}^{-1}\{\mathcal{I}_{\mathcal{Q}_{g,V,y}}\}[\psi]\bigr| \le C\|\psi\|_{\Xi^k}.\]

  3. Fourier-domain representer identity

    \[\mathcal{F}^{-1} \left\{ \mathcal{I}_{ \omega \; \mapsto \; \mathcal{Q}_{g,V,y}(\omega)\varphi_V(-\omega)} \right\} = \mathcal{I}_{\lambda_{g,V,y}} \qquad \text{in }\mathscr S'(\mathbb{R}^d)\]

Then \(\mathcal{F}^{-1}\{\mathcal{I}_{\mathcal{Q}_{g,V,y}}\}\) extends uniquely to a continuous linear functional on \(\Xi^k(\mathbb{R}^d;\mathbb{C})\), and its restriction to \(\mathcal{A}_V(\mathbb{R}^d)\) is the Tweedie functional \(\mathcal{T}_{g,V,y}\). Equivalently, for every \(f\in \mathcal{A}_V(\mathbb{R}^d)\) and every sequence \((f_n)_{n=1}^\infty\subset \mathscr S(\mathbb{R}^d)\) with \(\|f_n-f\|_{\Xi^k}\to 0\), \[\mathcal{T}_{g,V,y}[f] = \lim_{n\to\infty} \mathcal{F}^{-1}\{\mathcal{I}_{\mathcal{Q}_{g,V,y}}\}[f_n],\] and the limit is independent of the approximating sequence.

Theorem 2 turns the abstract existence of the Tweedie functional into a closed-form formula. The construction proceeds by identifying a complex-valued function \(\mathcal{Q}_{g,V,y}\) with three properties. Condition (i) is an integrability condition. It ensures that \(\mathcal{Q}_{g,V,y}\) defines a tempered distribution by integration. Its inverse Fourier transform is therefore well defined as a tempered distribution, and hence as a linear functional on the Schwartz space. Condition \((ii)\) is where the ambient space \(\Xi^k(\mathbb{R}^d;\mathbb{C})\) enters. It requires this Schwartz-level functional to be continuous with respect to the \(\Xi^k\)-norm, and therefore to extend continuously to \(\Xi^k(\mathbb{R}^d;\mathbb{C})\).

Conditions \((i)\) and \((ii)\) together ensure that \(\mathcal{Q}_{g,V,y}\) induces a well-defined continuous functional on \(\Xi^k(\mathbb{R}^d;\mathbb{C})\). They do not, by themselves, identify this functional with the Tweedie functional. Identification comes from Condition \((iii)\), the Fourier-domain representer identity: after accounting for the noise, the functional generated by \(\mathcal{Q}_{g,V,y}\) must agree with the functional induced by integration against \(\lambda_{g,V,y}\). Any function \(\mathcal{Q}_{g,V,y}\) satisfying this identity is called a Fourier-domain representer for \(\lambda_{g,V,y}\). When Conditions \((i)\)\((iii)\) all hold, the theorem shows that the Tweedie functional can be computed by evaluating the inverse Fourier transform of \(\mathcal{I}_{\mathcal{Q}_{g,V,y}}\) on Schwartz approximations to any \(V\)-admissible mixture and passing to the \(\Xi^k\)-limit.

Remark 4. Suppose further that \(\lambda_{g,V,y}\in L^1(\mathbb{R}^d;\mathbb{C})\). Under Assumption 2, one candidate Fourier-domain representer is \[\mathcal{Q}_{g,V,y}(\omega) = \frac{\widetilde{\lambda}_{g,V,y}(\omega)}{\varphi_V(-\omega)} \mathbb{1}\{\varphi_V(-\omega)\neq 0\}.\]

Indeed, for every \(\psi\in\mathscr S(\mathbb{R}^d)\), Fourier duality gives \[\begin{align} \mathcal{F}^{-1} \left\{ \mathcal{I}_{\omega\mapsto \mathcal{Q}_{g,V,y}(\omega)\varphi_V(-\omega)} \right\}[\psi]= \int_{\mathbb{R}^d} \widetilde{\lambda}_{g,V,y}(\omega)\psi^\sharp(\omega)\,d\omega = \int_{\mathbb{R}^d} \lambda_{g,V,y}(\omega)\psi(\omega)\,d\omega = \mathcal{I}_{\lambda_{g,V,y}}[\psi]. \end{align}\] Thus Condition (iii) of Theorem 2 holds.

The preceding remark shows that, when \(\lambda_{g,V,y}\) is integrable, a Fourier-domain representer is always available and can be computed directly. Moreover, this integrability requirement is often mild. Under Gaussian noise, for example, the exponential decay of the noise density accommodates functions \(g\) with polynomial growth of arbitrary degree. In such cases, because a Fourier-domain representer is already known, applying Theorem 2 only requires verifying the two analytic conditions, Conditions (i) and (ii), for the resulting \(\mathcal{Q}_{g,V,y}\). When \(\lambda_{g,V,y}\) is not integrable, a Fourier-domain representer may still be obtained by direct inspection of the Fourier-domain representer identity.11

Pragmatically, the theorem thus gives a three-step strategy for computing Tweedie functionals:

  1. Find a Fourier-domain representer \(\mathcal{Q}_{g,V,y}(\omega)\) and verify it defines a tempered distribution by integration.

  2. Compute the inverse Fourier transform \(\mathcal{F}^{-1}\{\mathcal{I}_{\mathcal{Q}_{g,V,y}}\}\) on Schwartz space \(\mathscr S(\mathbb{R}^d)\).

  3. Prove \(\Xi^k\)-continuity and compute the Tweedie functional evaluated at a \(V-\)mixture by taking the \(\Xi^k\)-limit along a Schwartz approximating sequence.

I now apply this strategy to recover the classical Tweedie formula.

Example 1 (Original Tweedie’s formula.). Suppose \(d=1\), \(Y=X+V\), \(X\perp\!\!\!\!\perp V\), and \(V\sim\mathcal{N}(0,\sigma^2)\). Let \(g(x)=x\), fix \(y\in\mathbb{R}\), and take \(k=1\). Since the Gaussian density belongs to \(C_0^\infty(\mathbb{R})\), the smoothness assumption holds. First, let’s compute a Fourier-domain representer. Here \(x \mapsto\lambda_{g,V,y}(x)=x f_V(y-x)\in\Xi^0(\mathbb{R};\mathbb{C})\), and \[\widetilde{\lambda}_{g,V,y}(\omega) = \bigl(y+i\sigma^2\omega\bigr)e^{i\omega y} e^{-\sigma^2\omega^2/2}.\] Since \(\varphi_V(-\omega)=e^{-\sigma^2\omega^2/2}\), the remark gives a Fourier-domain representer via \[\mathcal{Q}_{g,V,y}(\omega)=\dfrac{\widetilde{\lambda}_{g,V,y}(\omega)}{\varphi_V(-\omega)} = \bigl(y+i\sigma^2\omega\bigr)e^{i\omega y}.\] Second, since \(\mathcal{Q}_{g,V,y}\) grows at most linearly, it defines a tempered distribution by integration, and the standard transform identities [18] yield \[\mathcal{F}^{-1}\{\mathcal{I}_{\mathcal{Q}_{g,V,y}}\}[\psi] = y\psi(y)+\sigma^2\psi'(y), \qquad \psi\in\mathscr S(\mathbb{R}).\] Third, \[\left|y\psi(y)+\sigma^2\psi'(y)\right| \le \bigl(|y|+\sigma^2\bigr)\|\psi\|_{\Xi^1},\] so the \(\Xi^1\)-continuity condition holds. Therefore Theorem 2 implies that, for any \((f_n)_{n\ge1}\subset\mathscr S(\mathbb{R})\) with \(\|f_n-f_Y\|_{\Xi^1}\to0\), \[\mathcal{T}_{g,V,y}[f_Y] = \lim_{n\to\infty} \{y f_n(y)+\sigma^2 f_n'(y)\} = y f_Y(y)+\sigma^2 f_Y'(y),\] since \(f_n\to f_Y\) in \(\Xi^1\), implies both \(f_n(y)\to f_Y(y)\) and \(f_n'(y)\to f_Y'(y)\). Dividing by \(f_Y(y)\), whenever \(f_Y(y)>0\), gives \[\mathbb{E}[X\mid Y=y] = y+\sigma^2\frac{f_Y'(y)}{f_Y(y)}.\]

0.0.4.2 Tweedie formulas via approximation by continuous functions

Theorem 2 gives a systematic way to compute Tweedie representations when the Fourier-domain representer \(\mathcal{Q}_{g,V,y}\) defines a tempered distribution. Some functionals fall outside this setting. For example, the function \(g\) defining the estimand may be discontinuous. In such cases, we can still apply the strategy by approximating the original problem with instances for which the tools apply. The next result gives one such approximation argument.

Proposition 3 (Tweedie functionals via approximation). Let \((Y,X,V)\) satisfy Assumptions 2 and 3. Fix \(y\in\mathbb{R}^d\) and a measurable function \(g:\mathbb{R}^d\to\mathbb{R}\). Let \((g_n)_{n\ge1}\) be a sequence of measurable functions. Define \(\lambda_{n,g,V,y}(x)=g_n(x)f_V(y-x)\) and \(\lambda_{g,V,y}(x)=g(x)f_V(y-x)\). Assume that \(\lambda_{n,g,V,y} \in C_0(\mathbb{R}^d;\mathbb{C})\) for every \(n \geq 1\), that \(\lambda_{n,g,V,y}(x) \to \lambda_{g,V,y}(x)\) for all \(x\in\mathbb{R}^d\), and that \(\sup_{n\ge1}\|\lambda_{n,g,V,y}\|_\infty<\infty\). Then, for each \(n\ge1\), there exists a unique functional \(\mathcal{T}_{n,g,V,y}\in \mathcal{A}_V'(\mathbb{R}^d)\) such that \[\mathcal{T}_{n,g,V,y}[f_V*\mu] = \int_{\mathbb{R}^d}\lambda_{n,g,V,y}(x)\,d\mu(x), \qquad \mu\in\mathcal{M}(\mathbb{R}^d).\]

Moreover, there exists a unique continuous linear functional \(\mathcal{T}_{g,V,y}\in \mathcal{A}_V'(\mathbb{R}^d)\) such that \[\mathcal{T}_{g,V,y}[f_V*\mu] = \int_{\mathbb{R}^d}\lambda_{g,V,y}(x)\,d\mu(x), \qquad \mu\in\mathcal{M}(\mathbb{R}^d).\] In fact, for every \(f\in\mathcal{A}_V(\mathbb{R}^d)\), this map is given as a pointwise limit \[\mathcal{T}_{g,V,y}[f] = \lim_{n\to\infty} \mathcal{T}_{n,g,V,y}[f].\]

In particular, if \((Y,X,V)\) also satisfies Assumption 1, then \(f_Y=f_V*P_X\), and whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{1}{f_Y(y)} \lim_{n\to\infty} \mathcal{T}_{n,g,V,y}[f_Y].\]

The next example illustrates how this approximation argument produces a Tweedie representation beyond the direct scope of Theorem 2

Example 2 (Posterior distribution function under Gaussian noise.). Suppose \(d=1\), \(Y=X+V\), \(X\perp\!\!\!\!\perp V\), and \(V\sim \mathcal{N}(0,\sigma^2)\). We seek a Tweedie-type representation for the posterior distribution function, \(\mathbb{P}[X\le x\mid Y=y]\), which corresponds to the measurable function \(g_x(u)=\mathbb{1}\{u\le x\}\), \(x\in\mathbb{R}\). For \(n\ge1\), define the smooth approximation \[g_{n,x}(u) = \Phi\left(\frac{x+n^{-1/2}-u}{n^{-1}}\right), \qquad u\in\mathbb{R}.\]

It is straightforward to check that \((g_{n,x})_{n\ge 1}\) satisfies the conditions of Proposition 3. Moreover, each \(g_{n,x}\) gives

\[\begin{align} \mathcal{T}_{n,g_x,V,y}[f] &= f(y)\Phi\left(\frac{x+n^{-1/2}-y}{\sqrt{\sigma^2+n^{-2}}}\right) +\mathsf S_n[f], \quad f \in \mathcal{A}_V(\mathbb{R}),\\ \mathsf S_n[f] &\mathrel{\mathop{:}}=\sum_{k=1}^{\infty} \frac{(-1)^k}{k!} \left( \frac{\sigma^2}{\sqrt{\sigma^2+n^{-2}}} \right)^k \Phi^{(k)} \left( \frac{x+n^{-1/2}-y}{\sqrt{\sigma^2+n^{-2}}} \right) f^{(k)}(y). \end{align}\]

where \(\Phi\) is the cumulative distribution function of a standard normal variable. For each fixed \(n\), this series converges absolutely.12 Therefore, \[\begin{align} \mathbb{P}[X\le x\mid Y=y] &=\frac{1}{f_Y(y)} \lim_{n\to\infty} \mathcal{T}_{n,g_x,V,y}[f_Y]\\ &= \Phi\left(\frac{x-y}{\sigma}\right) + \frac{1}{f_Y(y)} \lim_{n\to\infty}\mathsf S_n[f_Y] . \end{align}\]

To the best of my knowledge, this representation is new. It also has a simple interpretation. The first term, \(\Phi((x-y)/\sigma)\), is the posterior distribution function obtained under a flat, or locally uninformative, prior on \(X\). The remaining terms correct this flat-prior approximation by using information in the marginal density \(f_Y\) and its derivatives.

The formula also shows why posterior distribution functions are harder to recover than posterior means. In the Gaussian case, the posterior mean depends only on the first derivative of \(f_Y\), whereas the posterior cdf involves derivatives of \(f_Y\) of all orders. In special cases, moreover, the expression simplifies. For example, if \(X\sim\mathcal{N}(m,\tau^2)\), then \(X\mid Y=y \sim \mathcal{N}\left( \frac{\sigma^2m+\tau^2y}{\sigma^2+\tau^2}, \frac{\sigma^2\tau^2}{\sigma^2+\tau^2} \right)\). In this case, the derivatives of \(f_Y\) are controlled, and the limit in \(n\) can be interchanged with the series. Mehler’s formula [55] then confirms the closed-form series expansion \[\frac{1}{f_Y(y)} \sum_{k=0}^{\infty} \frac{(-1)^k \sigma^k}{k!} \Phi^{(k)} \left( \frac{x-y}{\sigma} \right) f_Y^{(k)}(y) = \Phi\left( \frac{ x-\frac{\sigma^2m+\tau^2y}{\sigma^2+\tau^2} }{ \sqrt{\frac{\sigma^2\tau^2}{\sigma^2+\tau^2}} } \right)=\mathbb{P}[X\le x\mid Y=y].\]

0.0.5 Applications of Tweedie Calculus↩︎

This section illustrates the range of Tweedie calculus through four applications. First, I derive posterior mean formulas for several non-Gaussian additive-noise models. Second, I identify cases in which Tweedie functionals can be written as expectations of explicit functions of the observed variable. Third, I study posterior functionals under the conventional Laplace mechanism used in differential privacy. Fourth, I extend the calculus to the heteroskedastic Gaussian sequence model by conditioning on the potentially random noise covariance structure. The detailed calculations supporting these applications are relegated to Appendix 1.0.1.5.

0.0.5.1 Posterior means beyond Gaussian noise

The first application concerns posterior means under additive noise laws other than the Gaussian. As noted before, the three-step strategy from Section 0.0.4 can be applied case by case. Alternatively, the same tools can also identify entire families of Tweedie functionals from the structure of their Fourier-domain representers. The next proposition gives one such characterization. It generalizes the original Gaussian calculation by showing that certain factorizations of \(\mathcal{Q}_{g,V,y}\) yield weighted-derivative representations.

Proposition 4 (Tweedie representation via factorization of measures). Fix \(y\in\mathbb{R}^d\) and let \(g:\mathbb{R}^d\to\mathbb{R}\) be measurable. Suppose that \((Y,X,V)\) satisfies Assumptions 1, 2, 3, and 4 with smoothness order \(k\in\mathbb{N}_0\). Assume \(\lambda_{g,V,y} \in C_0(\mathbb{R}^d,\mathbb{C})\). Suppose there exists a family of finite complex Borel measures \(\{\mu_\alpha:|\alpha|\le k\}\subset \mathcal{M}(\mathbb{R}^d)\) such that the function \[\mathcal{Q}_{g,V,y}(\omega) = \sum_{|\alpha|\le k}(i\omega)^\alpha\varphi_{\mu_\alpha}(\omega), \qquad \varphi_\mu(\omega) \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} e^{i\omega^\top x}\,d\mu(x), \qquad\text{for Lebesgue-a.e. }\omega\in\mathbb{R}^d.\] is a Fourier-domain representer for \(\lambda_{g,V,y}\). Then, for every \(f\in\mathcal{A}_V(\mathbb{R}^d)\), \[\mathcal{T}_{g,V,y}[f] = \sum_{|\alpha|\le k} \int_{\mathbb{R}^d}\partial^\alpha f(z)\,d\mu_\alpha(z).\] In particular, whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{1}{f_Y(y)} \sum_{|\alpha|\le k} \int_{\mathbb{R}^d}\partial^\alpha f_Y(z)\,d\mu_\alpha(z).\]

Proposition 4 covers the case in which the Fourier-domain representer \(\mathcal{Q}_{g,V,y}\) factors into powers of \(\omega\) whose coefficients are Fourier–Stieltjes transforms of finitely many measures. In this case, the Tweedie functional is a finite linear combination of weighted derivatives of \(f_Y\). The original Tweedie formula is one instance of this factorization. We now turn to a non-Gaussian example and show that the same method applies just as naturally under Laplace noise.

Example 3 (Posterior mean under Laplace noise.). Suppose \(d=1\), \(Y=X+V\), \(X \perp\!\!\!\!\perp V\), and \(V\) has Laplace density \(f_V(u)=(2b)^{-1}e^{-|u|/b}\), with \(b>0\). Let \(g(x)=x\). Since \(f_V\in C_0(\mathbb{R})\), take \(k=0\). For fixed \(y\in\mathbb{R}\), \[\widetilde{\lambda}_{g,V,y}(\omega) = e^{i\omega y} \left( \frac{y}{1+b^2\omega^2} + \frac{2ib^2\omega}{(1+b^2\omega^2)^2} \right).\] Since \(\varphi_V(-\omega)=(1+b^2\omega^2)^{-1}\), the quotient construction gives a Fourier-domain representer for \(\lambda_{g,V,y}\): \[\mathcal{Q}_{g,V,y}(\omega)=\dfrac{\widetilde{\lambda}_{g,V,y}(\omega)}{\varphi_V(-\omega)} = \left( y+\frac{2ib^2\omega}{1+b^2\omega^2} \right)e^{i\omega y}.\] Now \(e^{i\omega y}=\varphi_{\delta_y}(\omega)\). If \(\nu_y\) denotes the finite signed measure with density \(d\nu_y(z)=\operatorname{sgn}(z-y)e^{-|z-y|/b}\,dz\), then

\[\varphi_{\nu_y}(\omega) = \frac{2ib^2\omega}{1+b^2\omega^2}e^{i\omega y} \qquad \text{ and } \qquad \mathcal{Q}_{g,V,y}(\omega) =y\,\varphi_{\delta_y}(\omega)+\varphi_{\nu_y}(\omega)= \varphi_{y\delta_y+\nu_y}(\omega).\]

By Proposition 4, with \(\mu_0=y\delta_y+\nu_y\), whenever \(f_Y(y)>0\), \[\mathbb{E}[X\mid Y=y] = y+ \frac{1}{f_Y(y)} \int_{\mathbb{R}} \operatorname{sgn}(z-y)e^{-|z-y|/b}f_Y(z)\,dz.\]

Other families are developed using the same techniques in Appendix 1.0.1.5.1. I conclude this subsection by illustrating the flexibility of the method across several noise distributions. Table [tab:noise-families] reports posterior mean representations for these noise laws, with the corresponding derivations collected in Appendix 1.0.1.5.2.

Several comments are in order. First, despite their analytic differences, the resulting decision rules share a common shrinkage form. Each posterior mean equals the observation, after correcting for the noise location, plus a normalized adjustment that depends only on the observed marginal density \(f_Y\). Thus the unknown prior distribution enters only through \(f_Y\), and the adjustment can be interpreted as a shrinkage or correction term. The form of this term, however, depends sharply on the noise law.

Second, the table shows that statistical difficulty is distribution-specific. For Gaussian noise, the correction is local: it depends only on \(f_Y(y)\) and \(f_Y'(y)\). This locality appears to be exceptional. The other entries involve nonlocal functionals of \(f_Y\). Notably, these pose a lower estimation difficulty.

[ht]
\centering
\scriptsize                     \setlength{\tabcolsep}{3.5pt}  \renewcommand{\arraystretch}{1.0} 
\begin{threeparttable}
\caption{Posterior mean Tweedie representations for several additive-noise models.}
\label{tab:noise-families}
\begin{tabular}{@{}lcc>{$\displaystyle}l<{$}@{}}
\toprule
Noise law
& $f_V(v)$
& $\varphi_V(\omega)$
& \multicolumn{1}{c@{}}{Tweedie representation of $\mathbb E[X\mid Y=y]$} \\
\midrule
\multicolumn{4}{@{}l}{\emph{Two-sided laws on $\mathbb R$}}\\[1pt]
\begin{tabular}[t]{@{}l@{}}
$\mathrm{Normal}(\mu,\sigma^2)$\\[-1pt]
$\mu\in\mathbb R,\;\sigma>0$
\end{tabular}
& $\displaystyle \frac{1}{\sqrt{2\pi}\sigma}\exp\!\left(-\frac{(v-\mu)^2}{2\sigma^2}\right)$
& $\displaystyle e^{i\mu\omega-\sigma^2\omega^2/2}$ 
& y-\mu+\sigma^2\frac{f_Y'(y)}{f_Y(y)}
\\
\addlinespace[\smallskipamount]
\begin{tabular}[t]{@{}l@{}}
$\mathrm{Generalized\;Laplace}(\mu,b,\lambda)$\\[-1pt]
$\mu\in\mathbb R,\;b>0,\;\lambda>\frac12$
\end{tabular}
& $\displaystyle \frac{1}{\sqrt{\pi}\,\Gamma(\lambda)\,b}\Bigl(\frac{|v-\mu|}{2b}\Bigr)^{\lambda-\frac12}
K_{\lambda-\frac12}\!\Bigl(\frac{|v-\mu|}{b}\Bigr)$
& $\displaystyle e^{i\mu\omega}(1+b^2\omega^2)^{-\lambda}$
& \begin{aligned}[t]
y-\mu
&+\frac{\lambda}{f_Y(y)}
\left[
\int_{\mathbb R}\operatorname{sgn}(z-y)e^{-|z-y|/b}f_Y(z)\,dz
\right]
\end{aligned}
\\
\addlinespace[\smallskipamount]
\begin{tabular}[t]{@{}l@{}}
$\mathrm{Laplace}(\mu,b)$\\[-1pt]
$\mu\in\mathbb R,\;b>0$
\end{tabular}
& $\displaystyle \frac{1}{2b}e^{-|v-\mu|/b}$
& $\displaystyle \frac{e^{i\mu\omega}}{1+b^2\omega^2}$
& \begin{aligned}[t]
y-\mu
&+\frac{1}{f_Y(y)}
\left[
\int_{\mathbb R}\operatorname{sgn}(z-y)e^{-|z-y|/b}f_Y(z)\,dz
\right]
\end{aligned}
\\
\addlinespace[\smallskipamount]
\begin{tabular}[t]{@{}l@{}}
$\mathrm{Asymmetric\;Laplace}(\mu,b_-,b_+)$\\[-1pt]
$\mu\in\mathbb R,\;b_->0,\;b_+>0$
\end{tabular}
& $\displaystyle \frac{1}{b_-+b_+} \left(\exp\!\Bigl(\frac{v-\mu}{b_-}\Bigr)\mathbf{1}_{\{v<\mu\}}
+\exp\!\Bigl(-\frac{v-\mu}{b_+}\Bigr)\mathbf{1}_{\{v\ge \mu\}}\right)$
& $\displaystyle \frac{e^{i\mu\omega}}{(1+i b_-\omega)(1-i b_+\omega)}$
& y-\mu+
\frac{1}{f_Y(y)}
\left[
\int_y^\infty e^{-(z-y)/b_-}f_Y(z)\,dz
-
\int_{-\infty}^y e^{(z-y)/b_+}f_Y(z)\,dz
\right]
\\
\addlinespace[\smallskipamount]
\begin{tabular}[t]{@{}l@{}}
$\mathrm{Logistic}(\mu,s)$\\[-1pt]
$\mu\in\mathbb R,\;s>0$
\end{tabular}
& $\displaystyle \frac{e^{-(v-\mu)/s}}{s\bigl(1+e^{-(v-\mu)/s}\bigr)^2}$
& $\displaystyle e^{i\mu\omega}\frac{\pi s\omega}{\sinh(\pi s\omega)}$
& \begin{aligned}[t]
y-\mu
&+\frac{1}{f_Y(y)}
\left[
\int_0^\infty
\frac{f_Y(y+t)-f_Y(y-t)}{e^{t/s}-1}\,dt
\right]
\end{aligned}
\\
\addlinespace[\smallskipamount]

\begin{tabular}[t]{@{}l@{}}
$\mathrm{Gumbel}(\mu,\beta)$\\[-1pt]
$\mu\in\mathbb R,\;\beta>0$
\end{tabular}
& $\displaystyle \frac{1}{\beta}\exp\!\left[-\frac{v-\mu}{\beta}-e^{-(v-\mu)/\beta}\right]$
& $\displaystyle e^{i\mu\omega}\Gamma(1-i\beta\omega)$
& \begin{aligned}[t]
y-\mu-\beta\gamma_E
&+\frac{1}{f_Y(y)}
\left[
\int_0^\infty
\frac{f_Y(y)-f_Y(y-u)}{e^{u/\beta}-1}\,du
\right]
\end{aligned}
\\
\addlinespace[\smallskipamount]

\begin{tabular}[t]{@{}l@{}}
$\mathrm{Cauchy}(\mu,\gamma)$\\[-1pt]
$\mu\in\mathbb R,\;\gamma>0$
\end{tabular}
& $\displaystyle \frac{1}{\pi}\frac{\gamma}{(v-\mu)^2+\gamma^2}$
& $\displaystyle e^{i\mu\omega-\gamma|\omega|}$
& y-\mu-\gamma\,\frac{\mathcal H[f_Y](y)}{f_Y(y)}
\\
\addlinespace[\smallskipamount]

\begin{tabular}[t]{@{}l@{}}
$\mathrm{Hyperbolic\;Secant}(\mu,s)$\\[-1pt]
$\mu\in\mathbb R,\;s>0$
\end{tabular}
& $\displaystyle \frac{1}{2s}\operatorname{sech}\!\left(\frac{\pi(v-\mu)}{2s}\right)$
& $\displaystyle e^{i\mu\omega}\operatorname{sech}(s\omega)$
& \begin{aligned}[t]
y-\mu
&+\frac{1}{f_Y(y)}
\left[
\int_0^\infty
\frac{f_Y(y+t)-f_Y(y-t)}
{2\sinh\!\left(\frac{\pi t}{2s}\right)}\,dt
\right]
\end{aligned}
\\
\addlinespace[\smallskipamount]

\addlinespace[2pt]
\multicolumn{4}{@{}l}{\emph{One-sided laws on $(0,\infty)$}}\\[1pt]

\begin{tabular}[t]{@{}l@{}}
$\mathrm{Gamma}(\alpha,\theta)$\\[-1pt]
$\alpha>1,\;\theta>0$
\end{tabular}
& $\displaystyle \frac{1}{\Gamma(\alpha)\theta^\alpha}v^{\alpha-1}e^{-v/\theta}\mathbf{1}_{\{v>0\}}$
& $\displaystyle (1-i\theta\omega)^{-\alpha}$
& \begin{aligned}[t]
y
&-\frac{\alpha}{f_Y(y)}
\left[
\int_{-\infty}^y e^{(z-y)/\theta}f_Y(z)\,dz
\right]
\end{aligned}
\\


\addlinespace[\smallskipamount]

\begin{tabular}[t]{@{}l@{}}
$\mathrm{Noncentral}\;\chi^2_\nu(\delta)$\\[-1pt]
$\nu>2,\;\delta\ge 0$
\end{tabular}
&
$\begin{array}[t]{@{}ll@{}}
\displaystyle
\frac{1}{2}e^{-(v+\delta)/2}
\left(\frac{v}{\delta}\right)^{\nu/4-1/2}
I_{\nu/2-1}\!\bigl(\sqrt{\delta v}\bigr)
\mathbf 1_{\{v>0\}},
& \;\delta>0, \\[7pt]
\displaystyle
\frac{1}{2^{\nu/2}\Gamma(\nu/2)}
v^{\nu/2-1}e^{-v/2}\mathbf 1_{\{v>0\}},
& \;\delta=0
\end{array}$
&
$\displaystyle
(1-2i\omega)^{-\nu/2}
\exp\!\Bigl(\frac{i\delta\omega}{1-2i\omega}\Bigr)$
&
y-
\frac{1}{f_Y(y)}
\left[
\frac{\nu}{2}\int_{-\infty}^y e^{(z-y)/2}f_Y(z)\,dz
+
\frac{\delta}{4}\int_{-\infty}^y (y-z)e^{(z-y)/2}f_Y(z)\,dz
\right]
\\[2pt]


\addlinespace[\smallskipamount]

\begin{tabular}[t]{@{}l@{}}
$\mathrm{Inverse\;Gaussian}(\mu,\lambda)$\\[-1pt]
$\mu>0,\;\lambda>0$
\end{tabular}
& $\displaystyle \left(\frac{\lambda}{2\pi v^3}\right)^{1/2}
\exp\!\left(-\frac{\lambda(v-\mu)^2}{2\mu^2v}\right)\mathbf{1}_{\{v>0\}}$
& $\displaystyle \exp\!\left[\frac{\lambda}{\mu}\left(1-\sqrt{1-\frac{2i\mu^2\omega}{\lambda}}\right)\right]$
& y-
\frac{1}{f_Y(y)}
\left[
\sqrt{\frac{\lambda}{2\pi}}
\int_{-\infty}^y
(y-z)^{-1/2}
\exp\!\left(-\frac{\lambda(y-z)}{2\mu^2}\right)
f_Y(z)\,dz
\right]
\\[2pt]

\bottomrule
\end{tabular}

\begin{tablenotes}[flushleft]
\footnotesize
\item \textit{Notes:} Parameter restrictions are displayed below each distribution and indicate the conditions under which the displayed Tweedie representation is derived in the appendix. Here $\Gamma$ denotes the Euler gamma function, $I_\nu$ and $K_\nu$ the modified Bessel functions of the first and second kind, respectively, $\mathcal H$ the Hilbert transform, $\gamma_E$ the Euler--Mascheroni constant, $\operatorname{sgn}(x)$ the sign function, and $\operatorname{sech}(x)=2/(e^x+e^{-x})$.
\end{tablenotes}

\end{threeparttable}

Finally, the table illustrates the value of recasting the problem as Fourier calculus. The Cauchy entry is especially instructive. Its posterior mean involves the Hilbert transform of the observed density, a representation that would be hard to guess without the language of tempered distributions. In the present approach, it follows from the standard identity identifying the Hilbert transform with the inverse Fourier transform of the integration map defined by \(\omega\mapsto -i\operatorname{sgn}(\omega)\) [56].

0.0.5.2 Tweedie functionals given as an expectation

Appendix 1.0.1.3 considers Tweedie representations in the case where the Fourier-domain representer is integrable, \(\mathcal{Q}_{g,V,y}\in L^1(\mathbb{R}^d;\mathbb{C})\). In this regime, the Tweedie functional can be written as an expectation of the inverse Fourier transform of \(\mathcal{Q}_{g,V,y}\).

This representation connects the framework to the classical literature on unbiased estimation of functions of latent variables under additive noise. In the Gaussian case, the problem goes back to [57]. The present result obtains the representation in closed form from the Fourier-domain representer. Other frameworks, notably [58] and [59], derive related formulas through power-series expansions of analytic functions.

0.0.5.3 Functionals under the conventional Laplace mechanism

Differential privacy is a standard framework for protecting individual privacy in statistical and machine-learning applications. A canonical way to achieve differential privacy is to add noise to the output of a query before release. For vector-valued queries, such as Census counts across geographic or demographic cells, the conventional Laplace mechanism adds independent one-dimensional Laplace noise to each coordinate. This mechanism is defined in [60] and gives standard differential privacy guarantees [60]..

This subsection studies Tweedie representations for posterior functionals after such a release. Motivated by the Laplace mechanism, consider the model \[Y=X+V, \qquad X\perp\!\!\!\!\perp V, \qquad V=(V_1,\ldots,V_d), \qquad V_j\overset{\mathrm{i.i.d.}}{\sim}\operatorname{Lap}(0,b).\]

Table [tab:laplace-tweedie-functionals] collects several Tweedie representations for the product-Laplace model in dimension one. Appendix 1.0.1.5.3 provides the derivations and extends the posterior mean, posterior covariance matrix, and posterior moment generating function formulas to arbitrary dimensions.

4pt

@ccc@ Name of functional & \(g(x)\) & \(\mathbb{E}[g(X)\mid Y=y]\)

Posterior mean & \(\displaystyle x\) &
Posterior second moment & \(\displaystyle x^2\) &
Posterior moment generating function & \(\displaystyle e^{tx},\quad |t|<1/b\) &
Posterior distribution function at \(a\) & \(\displaystyle \mathbf{1}\{x\le a\},\quad a\in\mathbb{R}\) &
Posterior squared risk around \(a\) & \(\displaystyle (x-a)^2,\quad a\in\mathbb{R}\) &

Posterior hinge loss around \(a\) & \(\displaystyle (x-a)_+,\quad a\in\mathbb{R}\) &

Posterior pinball loss around \(a\) & \(\displaystyle \rho_\tau(x-a), \; a\in\mathbb{R},\;\tau\in(0,1)\) & \(\displaystyle \begin{aligned} & \tau(y-a)_+ + (1-\tau)(a-y)_+ + \frac{\tau}{f_Y(y)} \int_{0}^{\infty} e^{-|u|/b}f_Y(y+u)\,du + \frac{1-\tau}{f_Y(y)} \int_{-\infty}^{0} e^{-|u|/b}f_Y(y+u)\,du \\ &\quad - \frac{1}{f_Y(y)} \int_{\min(0,a-y)}^{\max(0,a-y)} e^{-|u|/b}f_Y(y+u)\,du - \frac{b e^{-|y-a|/b}f_Y(a)}{2f_Y(y)} \end{aligned}\)


Posterior variance & \(\displaystyle \text{--}\) &

Notes: Throughout, \(Y=X+V\), \(X\perp\!\!\!\!\perp V\), \(V\sim\operatorname{Laplace}(0,b)\), \(b>0\), and \(f_Y(y)>0\). The operator \(D_+\) is the right derivative of the marginal density with respect to its scalar argument: \(D_+f_Y(a)=\lim_{h\downarrow0}\{f_Y(a+h)-f_Y(a)\}/h\). Here \((z)_+=\max\{z,0\}\), and \(\rho_\tau(z)=\tau z_+ +(1-\tau)(-z)_+\) for \(\tau\in(0,1)\).

0.0.5.4 Tweedie representations in the heteroskedastic Gaussian sequence model

The final application considers the heteroskedastic Gaussian sequence model. Its distinctive feature is that the noise covariance varies across units and may be statistically related to the latent parameter. This setting arises naturally in empirical Bayes problems with many noisy estimates, especially in economics and related social sciences.13 A common interpretation in these settings is that \(Y\) is an estimator of a latent parameter \(X\), constructed from a sample mean or, more generally, from an asymptotically linear statistic. The Gaussian specification formalizes the normal approximation implicit in standard large-sample inference for such estimators. Heteroskedasticity arises because sample sizes, sampling designs, or underlying population variability differ across units, making the covariance matrix unit-specific. It is therefore natural to model \((X,\Sigma)\) as drawn from a joint superpopulation distribution \(P_{X,\Sigma}\).

Formally, let \(\mathbb{S}_{++}^d\) denote the set of symmetric positive definite \(d\times d\) matrices. The model is \[Y=X+\Sigma^{1/2}V,\] where \(V\sim\mathcal{N}(0,I_d)\), \((X,\Sigma)\sim P_{X,\Sigma}\), and \((X,\Sigma)\perp\!\!\!\!\perp V\). It is common practice to consider \(\Sigma\) to be known and equal to a sample-based estimate.

At first glance, heteroskedasticity seems to put the model outside the scope of the preceding sections, since there is no single fixed noise distribution to deconvolve. The key observation is that, after conditioning on \(\Sigma=\Sigma_0\) and standardizing by \(\Sigma_0^{-1/2}\), the model becomes an additive Gaussian model with identity noise covariance.14 The results from Sections 0.0.3 and 0.0.4 can therefore be applied conditionally, yielding Tweedie representations in terms of the conditional density \(f_{Y\mid\Sigma}(\cdot\mid\Sigma_0)\).

Critically, this conditional approach does not require an explicit model for the dependence between the latent parameter \(X\) and the noise covariance \(\Sigma\). This distinguishes the approach from the existing empirical Bayes literature on heteroskedastic normal means, which imposes parametric structure, or other restrictions, on the joint distribution \(P_{X,\Sigma}\); see [5], [66][71].

For a measurable function \(g:\mathbb{R}^d\to\mathbb{R}\), the objects of interest in this section are conditional posterior functionals of the form \[\mathbb{E}\!\left[g(X)\mid Y=y,\Sigma=\Sigma_0\right].\] If \(\Sigma\) were degenerate at \(\Sigma_0\in\mathbb{S}_{++}^d\), this would reduce to the usual posterior quantity under Gaussian noise with covariance \(\Sigma_0\). In the general case, however, \(\Sigma\) is random, so the model is not initially of the additive-noise form studied in the previous sections. Conditioning on \(\Sigma=\Sigma_0\) removes this difficulty. To see this, define \[Z\mathrel{\mathop{:}}=\Sigma^{-1/2}Y, \qquad W\mathrel{\mathop{:}}=\Sigma^{-1/2}X.\]

Then, conditional on \(\Sigma=\Sigma_0\), we have \(Z=W+V\), \(W\perp\!\!\!\!\perp V\), \(V\sim\mathcal{N}(0,I_d)\). In particular, \[\varphi_{Z\mid \Sigma}(\omega\mid \Sigma_0) = \varphi_{W\mid \Sigma}(\omega\mid \Sigma_0)\varphi_V(\omega).\]

Thus, conditional on \(\Sigma=\Sigma_0\), the standardized model satisfies the same structural conditions as the additive Gaussian model studied in Sections 0.0.3 and 0.0.4. The results developed there therefore apply conditional on \(\Sigma\), and hence pointwise in \(\Sigma_0\). The next proposition records this implication formally.

Proposition 5 (Conditional Tweedie representation in the heteroskedastic Gaussian sequence model). Fix \(y\in\mathbb{R}^d\), and for \(\Sigma_0\in\mathbb{S}_{++}^d\), set \(z_0\mathrel{\mathop{:}}=\Sigma_0^{-1/2}y\). Let \(g:\mathbb{R}^d\to\mathbb{R}\) be measurable. Then the following statements hold for \(P_\Sigma\)-almost every \(\Sigma_0\).

  1. \(f_{Z\mid \Sigma}(z_0\mid \Sigma_0)>0\), and whenever the right-hand side below is well defined, \[\mathbb{E}[g(X)\mid Y=y,\Sigma=\Sigma_0] = \frac{ \displaystyle \int_{\mathbb{R}^d} g(\Sigma_0^{1/2}w)\phi(z_0-w)\, dP_{W\mid\Sigma}(w\mid\Sigma_0) }{ f_{Z\mid\Sigma}(z_0\mid\Sigma_0) }.\]

  2. Define \(\lambda_{g,y,\Sigma_0}(w) \mathrel{\mathop{:}}= g(\Sigma_0^{1/2}w)\phi(z_0-w)\). If \(\lambda_{g,y,\Sigma_0}\in C_0(\mathbb{R}^d;\mathbb{C})\), then there exists a unique continuous linear functional \(\mathcal{T}_{g,y,\Sigma_0}\in \mathcal{A}_V'(\mathbb{R}^d)\), such that \[\mathcal{T}_{g,y,\Sigma_0}[f] = \int_{\mathbb{R}^d} \lambda_{g,y,\Sigma_0}(w)\,d\mu(w) \qquad \text{for every } f=\phi*\mu \in \mathcal{A}_V(\mathbb{R}^d).\] In particular, \[\mathcal{T}_{g,y,\Sigma_0} \!\left[f_{Z\mid\Sigma}(\cdot\mid\Sigma_0)\right] = \int_{\mathbb{R}^d} \lambda_{g,y,\Sigma_0}(w)\, dP_{W\mid\Sigma}(w\mid\Sigma_0),\] and therefore \[\mathbb{E}[g(X)\mid Y=y,\Sigma=\Sigma_0] = \frac{ \mathcal{T}_{g,y,\Sigma_0} \!\left[f_{Z\mid\Sigma}(\cdot\mid\Sigma_0)\right] }{ f_{Z\mid\Sigma}(z_0\mid\Sigma_0) }.\]

  3. Suppose, in addition to the condition in part (b), that there exists a Fourier-domain representer \(\mathcal{Q}_{g,y,\Sigma_0}\) for \(\lambda_{g,y,\Sigma_0}\) such that conditions (i) and (ii) of Theorem 2 hold for some \(N\ge0\) and \(k\ge0\). Then, for every \(f\in\mathcal{A}_V(\mathbb{R}^d)\) and every sequence \((f_n)_{n\ge1}\subset\mathscr S(\mathbb{R}^d)\) such that \(\|f_n-f\|_{\Xi^k}\to0\), \[\mathcal{T}_{g,y,\Sigma_0}[f] = \lim_{n\to\infty} \mathcal{F}^{-1} \{\mathcal{I}_{\mathcal{Q}_{g,y,\Sigma_0}}\}[f_n],\] and the limit is independent of the approximating sequence.

The proposition shows that, after conditioning on \(\Sigma=\Sigma_0\), the heteroskedastic problem can be treated using the same computational strategy developed in Section 0.0.4. The existence and computation results from that section therefore apply pointwise in \(\Sigma_0\), with the marginal density \(f_Y\) replaced by the conditional density \(f_{Z\mid\Sigma}(\cdot\mid\Sigma_0)\), or equivalently by \(f_{Y\mid\Sigma}(\cdot\mid\Sigma_0)\) after the change of variables.

4pt

@c>

p0.225c>p0.135c>p0.615c@

Name of functional & \(g(x)\) & \(\mathbb{E}[g(X)\mid Y=y,\Sigma=\sigma^2]\)

Posterior mean & \(\displaystyle x\) &
Posterior second moment & \(\displaystyle x^2\) &
Posterior moment generating function & \(\displaystyle e^{tx},\quad t\in\mathbb{R}\) &
Posterior \(k\)-th raw moment & \(\displaystyle x^k,\quad k\in\mathbb{N}\) &
Posterior \(2m\)-risk around \(a\) & \(\displaystyle |x-a|^{2m},\quad a\in\mathbb{R},\;m\in\mathbb{N}\) &
Posterior distribution function at \(a\) & \(\displaystyle \mathbf{1}\{x\le a\},\quad a\in\mathbb{R}\) &
Posterior hinge loss around \(a\) & \(\displaystyle (x-a)_+,\quad a\in\mathbb{R}\) & \(\displaystyle \begin{aligned} & \sigma\phi\!\left(\frac{a-y}{\sigma}\right) + (y-a) \left\{ 1-\Phi\!\left(\frac{a-y}{\sigma}\right) \right\} + \sigma^2 \left\{ 1-\Phi\!\left(\frac{a-y}{\sigma}\right) \right\} \frac{\partial_y f_{Y\mid\Sigma}(y\mid\sigma^2)}{f_{Y\mid\Sigma}(y\mid\sigma^2)} \\ &\quad+ \frac{1}{f_{Y\mid\Sigma}(y\mid\sigma^2)} \lim_{n\to\infty} \sum_{\ell=2}^{\infty} \frac{(-1)^\ell}{\ell!} \left( \frac{\sigma^2}{\sqrt{\sigma^2+n^{-2}}} \right)^\ell \sqrt{\sigma^2+n^{-2}} \Phi^{(\ell-1)} \!\left( \frac{a+n^{-1/2}-y}{\sqrt{\sigma^2+n^{-2}}} \right) \partial_y^\ell f_{Y\mid\Sigma}(y\mid\sigma^2) \end{aligned}\)
Posterior absolute risk around \(a\) & \(\displaystyle |x-a|,\quad a\in\mathbb{R}\) & \(\displaystyle \begin{aligned} & 2\sigma\phi\!\left(\frac{a-y}{\sigma}\right) + (a-y) \left\{ 2\Phi\!\left(\frac{a-y}{\sigma}\right)-1 \right\} + \sigma^2 \left\{ 1-2\Phi\!\left(\frac{a-y}{\sigma}\right) \right\} \frac{\partial_y f_{Y\mid\Sigma}(y\mid\sigma^2)}{f_{Y\mid\Sigma}(y\mid\sigma^2)} \\ &\quad+ \frac{2}{f_{Y\mid\Sigma}(y\mid\sigma^2)} \lim_{n\to\infty} \sum_{\ell=2}^{\infty} \frac{(-1)^\ell}{\ell!} \left( \frac{\sigma^2}{\sqrt{\sigma^2+n^{-2}}} \right)^\ell \sqrt{\sigma^2+n^{-2}} \Phi^{(\ell-1)} \!\left( \frac{a+n^{-1/2}-y}{\sqrt{\sigma^2+n^{-2}}} \right) \partial_y^\ell f_{Y\mid\Sigma}(y\mid\sigma^2) \end{aligned}\)

Posterior variance & \(\displaystyle \text{--}\) &
Posterior \(k\)-th centered moment & \(\displaystyle \text{--}\) &

Notes: Throughout, \(\sigma>0\), \(f_{Y\mid\Sigma}(y\mid\sigma^2)>0\), and all derivatives are with respect to \(y\). Also, \(\Phi\) denotes the standard normal distribution function and \(\Phi^{(\ell)}\) its \(\ell\)-th derivative. Here \((z)_+=\max\{z,0\}\).

I now apply this conditional Tweedie calculus to a range of empirical Bayes estimands under this model. Table [tab:conditional-tweedie-functionals] summarizes the one-dimensional formulas. Appendix [A:Examples] provides the derivations and extends the formulas for the posterior mean, posterior covariance, and posterior moment generating function to arbitrary dimensions.

0.0.6 Conclusion↩︎

Under Gaussian noise, Tweedie’s formula expresses the posterior mean as a functional of the observed marginal density. This paper develops a general framework for analogous identities governing conditional expectations in additive-noise models. The main contribution is twofold. First, I characterize when posterior functionals admit a representation through a linear map acting on the observed density—a structure I call the Tweedie functional—and establish existence, uniqueness, and continuity under general conditions. Second, I provide a constructive approach based on Fourier analysis for deriving such representations, showing that the relevant operator can be obtained by extending the inverse Fourier transform of an explicitly characterized tempered distribution to the space of admissible observed densities.

This perspective turns the search for Tweedie-type formulas into a tractable problem in the calculus of tempered distributions. It recovers the classical Gaussian identity, yields new posterior-mean representations for a broad family of noise laws, and, in some cases, delivers expressions that can be unbiasedly estimated from the data. The applications also cover posterior functionals under the Laplace mechanism used in differential privacy. Together, these results show that the same Fourier-distributional framework can handle different noise structures and different posterior functionals.

The heteroskedastic application shows that the method applies to extensions of the standard additive model. By conditioning on the realized covariance matrix and applying the appropriate change of variables, the model regains the structure needed for the theory to apply. This yields Tweedie representations for posterior means and other functionals directly in terms of the observable conditional density, without imposing additional structure on the model.

Appendix for:

1 ↩︎

1.0.1 Appendix↩︎

1.0.1.1 Schwartz functions and tempered distributions

This appendix expands on the theory of tempered distributions used throughout the paper. We first define the topology on the Schwartz space, then describe the induced weak-\(\star\) topology on tempered distributions and the action of the Fourier transform by duality.

1.0.1.1.1 The Schwartz topology

Let \(\mathscr S(\mathbb{R}^d)\) denote the Schwartz space of complex-valued smooth functions: \[\mathscr S(\mathbb{R}^d) = \left\{ \psi\in C^\infty(\mathbb{R}^d;\mathbb{C}): \sup_{x\in\mathbb{R}^d} |x^\alpha \partial^\beta \psi(x)|<\infty \text{ for all multi-indices } \alpha,\beta \right\}.\] Following Chapter 8.1 of [72], define, for \(N\in\mathbb{N}_0\) and \(\alpha\in\mathbb{N}_0^d\), \[p_{N,\alpha}(\psi) \mathrel{\mathop{:}}= \sup_{x\in\mathbb{R}^d} (1+\|x\|_2)^N \left|\partial^\alpha\psi(x)\right|.\] The standard Schwartz topology is the locally convex topology generated by the seminorms \[\left\{ p_{N,\alpha}: N\in\mathbb{N}_0,\;\alpha\in\mathbb{N}_0^d \right\}.\] With this topology, \(\mathscr S(\mathbb{R}^d)\) is a Fréchet space [72], Proposition 8.2. Thus \[\psi_n\to\psi \quad\text{in } \mathscr S(\mathbb{R}^d)\] if and only if \[p_{N,\alpha}(\psi_n-\psi)\to0 \qquad \text{for every } N\in\mathbb{N}_0 \text{ and } \alpha\in\mathbb{N}_0^d .\]

It will be useful to work with the equivalent increasing family \[q_m(\psi) \mathrel{\mathop{:}}= \max_{\substack{0\le N\le m\\ |\alpha|\le m}} p_{N,\alpha}(\psi), \qquad m\in\mathbb{N}_0 .\] The seminorms \((q_m)_{m\ge0}\) generate the same topology as \((p_{N,\alpha})_{N,\alpha}\). Hence \[\psi_n\to\psi \quad\text{in } \mathscr S(\mathbb{R}^d) \quad\Longleftrightarrow\quad q_m(\psi_n-\psi)\to0 \text{ for every } m\in\mathbb{N}_0 .\]

1.0.1.1.2 Fourier transform on the Schwartz space

We use the Fourier transform convention \[\widetilde{\psi}(\omega) = \int_{\mathbb{R}^d} e^{i\omega^\top x}\psi(x)\,dx, \qquad \psi\in\mathscr S(\mathbb{R}^d).\] Under this convention, differentiation and multiplication satisfy, for \(j=1,\ldots,d\), \[\partial_{\omega_j}\widetilde{\psi}(\omega) = \widetilde{\,i x_j\psi\,}(\omega), \qquad \widetilde{\partial_{x_j}\psi}(\omega) = -i\omega_j\widetilde{\psi}(\omega).\] Consequently, each Schwartz seminorm of \(\widetilde{\psi}\) is controlled by finitely many Schwartz seminorms of \(\psi\). Equivalently, for every \(m\in\mathbb{N}_0\), there exist constants \(C_m>0\) and \(r_m\in\mathbb{N}_0\) such that \[q_m(\widetilde{\psi}) \le C_m q_{r_m}(\psi), \qquad \psi\in\mathscr S(\mathbb{R}^d).\] Thus the Fourier transform is continuous on \(\mathscr S(\mathbb{R}^d)\). The same statement holds for the inverse Fourier transform, so the Fourier transform is a continuous linear automorphism of \(\mathscr S(\mathbb{R}^d)\).

1.0.1.1.3 Tempered distributions and weak-\(\star\) convergence

The space of tempered distributions is the continuous dual of the Schwartz space: \[\mathscr S'(\mathbb{R}^d) \mathrel{\mathop{:}}= \bigl(\mathscr S(\mathbb{R}^d)\bigr)'.\] Thus \(T\in\mathscr S'(\mathbb{R}^d)\) is a continuous linear functional \[T:\mathscr S(\mathbb{R}^d)\to\mathbb{C} .\] Since the seminorms \((q_m)_{m\ge0}\) are increasing and generate the Schwartz topology, \(T\in\mathscr S'(\mathbb{R}^d)\) if and only if there exist \(C>0\) and \(m\in\mathbb{N}_0\) such that \[|T[\psi]| \le C q_m(\psi), \qquad \psi\in\mathscr S(\mathbb{R}^d).\] Equivalently, there exist \(C>0\) and a finite set \(F\subset \mathbb{N}_0\times\mathbb{N}_0^d\) such that \[|T[\psi]| \le C \sum_{(N,\alpha)\in F} p_{N,\alpha}(\psi), \qquad \psi\in\mathscr S(\mathbb{R}^d).\]

The weak-\(\star\) topology on \(\mathscr S'(\mathbb{R}^d)\) is the topology of pointwise convergence on \(\mathscr S(\mathbb{R}^d)\). Hence a net \((T_i)_{i\in I}\subset\mathscr S'(\mathbb{R}^d)\) converges to \(T\in\mathscr S'(\mathbb{R}^d)\) if and only if \[T_i[\psi]\to T[\psi] \qquad \text{for every } \psi\in\mathscr S(\mathbb{R}^d).\]

1.0.1.1.4 Fourier transform on tempered distributions

The Fourier transform on \(\mathscr S(\mathbb{R}^d)\) induces a Fourier transform on \(\mathscr S'(\mathbb{R}^d)\) by duality. With the convention above, define the inverse Fourier transform of \(T\in\mathscr S'(\mathbb{R}^d)\) by \[\mathcal{F}^{-1}\{T\}[\psi] = T[\psi^\sharp], \qquad \psi^\sharp(\omega) = (2\pi)^{-d}\widetilde{\psi}(-\omega).\] The map \(\psi\mapsto\psi^\sharp\) is continuous from \(\mathscr S(\mathbb{R}^d)\) into itself. Therefore \(\mathcal{F}^{-1}\{T\}\in\mathscr S'(\mathbb{R}^d)\).

The map \(T\mapsto\mathcal{F}^{-1}\{T\}\) is weak-\(\star\) continuous. Indeed, if \(T_i\to T\) weak-\(\star\), then, for every \(\psi\in\mathscr S(\mathbb{R}^d)\), \[\mathcal{F}^{-1}\{T_i\}[\psi] = T_i[\psi^\sharp] \to T[\psi^\sharp] = \mathcal{F}^{-1}\{T\}[\psi].\] The same argument applies to the Fourier transform. Thus the Fourier transform and its inverse are weak-\(\star\) continuous automorphisms of \(\mathscr S'(\mathbb{R}^d)\).

1.0.1.1.5 A sufficient condition for temperedness

The next lemma gives the temperedness condition used in the main text.

Lemma 2 (Weighted integrability implies temperedness). Let \(Q:\mathbb{R}^d\to\mathbb{C}\) be measurable. Suppose that, for some \(N\in\mathbb{N}_0\), \[A_N \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} \frac{|Q(\omega)|}{(1+\|\omega\|_2)^N}\,d\omega <\infty .\] Then the map \[\mathcal{I}_Q[\psi] \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} Q(\omega)\psi(\omega)\,d\omega, \qquad \psi\in\mathscr S(\mathbb{R}^d),\] is well-defined and belongs to \(\mathscr S'(\mathbb{R}^d)\).

Proof. Fix \(\psi\in\mathscr S(\mathbb{R}^d)\). By definition of \(p_{N,0}\), \[|\psi(\omega)| \le p_{N,0}(\psi)(1+\|\omega\|_2)^{-N}, \qquad \omega\in\mathbb{R}^d .\] Therefore \[|Q(\omega)\psi(\omega)| \le p_{N,0}(\psi) \frac{|Q(\omega)|}{(1+\|\omega\|_2)^N}.\] The right-hand side is integrable by assumption, so \(\mathcal{I}_Q[\psi]\) is well-defined. Moreover, \[|\mathcal{I}_Q[\psi]| \le A_N p_{N,0}(\psi).\] This seminorm bound proves that \(\mathcal{I}_Q\) is continuous on \(\mathscr S(\mathbb{R}^d)\). Hence \(\mathcal{I}_Q\in\mathscr S'(\mathbb{R}^d)\). ◻

1.0.1.2 Proofs omitted from the main text

This appendix collects proofs that are used in the main text.

1.0.1.2.1 Proof of Proposition 1

Proof. By independence, \[P_Y = P_X * P_V .\] Let \(A\subseteq\mathbb{R}^d\) be Borel. Since \(P_V(dv)=f_V(v)\,dv\), Tonelli’s theorem gives \[P_Y(A) = \iint \mathbf{1}_A(x+v) f_V(v)\,dv\,dP_X(x).\] For each fixed \(x\), the change of variables \(y=x+v\) gives \[\int \mathbf{1}_A(x+v) f_V(v)\,dv = \int_A f_V(y-x)\,dy .\] Hence \[P_Y(A) = \int_A \left\{ \int_{\mathbb{R}^d} f_V(y-x)\,dP_X(x) \right\} dy .\] Therefore \(P_Y\) is absolutely continuous with density \[f_Y(y) = \int_{\mathbb{R}^d} f_V(y-x)\,dP_X(x).\] ◻

1.0.1.2.2 Proof of Proposition 2

Proof. Surjectivity follows from the definition of \(\mathcal{A}_V(\mathbb{R}^d)\): \[\mathcal{A}_V(\mathbb{R}^d) = \mathcal{K}_V\bigl(\mathcal{M}(\mathbb{R}^d)\bigr).\]

It remains to prove injectivity. Since \(\mathcal{K}_V\) is linear, it is enough to show that its kernel is trivial. Let \(\mu\in\mathcal{M}(\mathbb{R}^d)\) satisfy \[\mathcal{K}_V[\mu] = f_V * \mu = 0 \qquad \text{in } L^1(\mathbb{R}^d;\mathbb{C}).\] Let \[\varphi_\mu(\omega) \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} e^{i\omega^\top x}\,d\mu(x), \qquad \omega\in\mathbb{R}^d,\] be the Fourier–Stieltjes transform of \(\mu\). Since \(\mu\) is finite, \(\varphi_\mu\) is bounded and continuous, with \[|\varphi_\mu(\omega)| \le \|\mu\|_{TV}, \qquad \omega\in\mathbb{R}^d .\]

Taking Fourier transforms yields \[\widetilde{\mathcal{K}_V[\mu]}(\omega) = \widetilde{(f_V * \mu)}(\omega) = \widetilde{f}_V(\omega)\varphi_\mu(\omega) = \varphi_V(\omega)\varphi_\mu(\omega), \qquad \omega\in\mathbb{R}^d .\] Here \(\widetilde{f}_V=\varphi_V\) because \(f_V\) is the density of \(P_V\). Since \(\mathcal{K}_V[\mu]=0\) in \(L^1(\mathbb{R}^d;\mathbb{C})\), its Fourier transform vanishes identically. Thus \[\varphi_V(\omega)\varphi_\mu(\omega) = 0, \qquad \omega\in\mathbb{R}^d .\]

Define \[D \mathrel{\mathop{:}}= \{\omega\in\mathbb{R}^d:\varphi_V(\omega)\neq 0\}.\] By Assumption 2, \(D^c\) has Lebesgue measure zero. Hence \(D\) is dense in \(\mathbb{R}^d\), because no nonempty open ball can be contained in \(D^c\). On \(D\), \[\varphi_\mu(\omega)=0.\] The continuity of \(\varphi_\mu\) extends this equality to all of \(\mathbb{R}^d\): \[\varphi_\mu(\omega)=0, \qquad \omega\in\mathbb{R}^d .\] By uniqueness of Fourier–Stieltjes transforms for finite complex measures, \(\mu=0\). Therefore \(\mathcal{K}_V\) is injective. ◻

1.0.1.2.3 Proof of Theorem 1

Proof. Define the linear functional \[I_\lambda:\mathcal{M}(\mathbb{R}^d)\to\mathbb{C}, \qquad I_\lambda[\mu] \mathrel{\mathop{:}}= \int_{\mathbb{R}^d}\lambda(x)\,d\mu(x).\] Since \(\lambda\in C_0(\mathbb{R}^d;\mathbb{C})\), it is bounded. Hence \[|I_\lambda[\mu]| \le \|\lambda\|_\infty \|\mu\|_{TV}, \qquad \mu\in\mathcal{M}(\mathbb{R}^d),\] so \(I_\lambda\) is continuous with respect to the total variation norm. By Proposition 2, the map \[\mathcal{K}_V: \bigl(\mathcal{M}(\mathbb{R}^d),\|\cdot\|_{TV}\bigr) \to \bigl(\mathcal{A}_V(\mathbb{R}^d),\|\cdot\|_{\mathcal{A}_V}\bigr)\] is an isometric isomorphism. We may therefore define \[\mathcal{T}_{\lambda,V} \mathrel{\mathop{:}}= I_\lambda\circ \mathcal{K}_V^{-1}.\] Equivalently, if \(f\in\mathcal{A}_V(\mathbb{R}^d)\) and \(\mu_f=\mathcal{K}_V^{-1}[f]\), then \[\mathcal{T}_{\lambda,V}[f] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu_f(x).\] This definition is unambiguous because the representing measure \(\mu_f\) is unique.

The same bound proves continuity. Indeed, for \(f\in\mathcal{A}_V(\mathbb{R}^d)\), let \(\mu_f=\mathcal{K}_V^{-1}[f]\). Then \[|\mathcal{T}_{\lambda,V}[f]| = |I_\lambda[\mu_f]| \le \|\lambda\|_\infty \|\mu_f\|_{TV} = \|\lambda\|_\infty \|f\|_{\mathcal{A}_V}.\] Thus \[\mathcal{T}_{\lambda,V}\in\mathcal{A}'_V(\mathbb{R}^d).\]

Now let \(\mu\in\mathcal{M}(\mathbb{R}^d)\). Since \(\mathcal{K}_V^{-1}[\mathcal{K}_V[\mu]]=\mu\), \[\mathcal{T}_{\lambda,V}\!\left[\mathcal{K}_V[\mu]\right] = I_\lambda[\mu] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu(x).\] This proves the representation formula. Under Assumptions 1 and 3, Proposition 1 gives \[f_Y = f_V * P_X = \mathcal{K}_V[P_X].\] Applying the representation formula with \(\mu=P_X\) yields \[\mathcal{T}_{\lambda,V}[f_Y] = \mathcal{T}_{\lambda,V}\!\left[\mathcal{K}_V[P_X]\right] = \int_{\mathbb{R}^d}\lambda(x)\,dP_X(x) = \Lambda_\lambda(P_X).\]

It remains to prove uniqueness. Let \(S\in\mathcal{A}'_V(\mathbb{R}^d)\) satisfy \[S\!\left[\mathcal{K}_V[\mu]\right] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu(x), \qquad \mu\in\mathcal{M}(\mathbb{R}^d).\] Since \(\mathcal{K}_V\) is onto \(\mathcal{A}_V(\mathbb{R}^d)\), every \(f\in\mathcal{A}_V(\mathbb{R}^d)\) can be written as \(f=\mathcal{K}_V[\mu]\) for some \(\mu\in\mathcal{M}(\mathbb{R}^d)\). Therefore \[S[f] = S\!\left[\mathcal{K}_V[\mu]\right] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu(x) = \mathcal{T}_{\lambda,V}\!\left[\mathcal{K}_V[\mu]\right] = \mathcal{T}_{\lambda,V}[f].\] Hence \(S=\mathcal{T}_{\lambda,V}\). ◻

1.0.1.2.4 Proof of Lemma 1

Proof. We prove the three assertions separately.

Part (a): completeness of \(\Xi^k\). Let \((\psi_n)_{n\ge1}\) be a Cauchy sequence in \(\Xi^k\). Since \[\|\psi\|_\infty\le \|\psi\|_{\Xi^k}, \qquad \|\psi\|_1\le \|\psi\|_{\Xi^k},\] the sequence \((\psi_n)\) is Cauchy both in \((C_0(\mathbb{R}^d;\mathbb{C}),\|\cdot\|_\infty)\) and in \((L^1(\mathbb{R}^d;\mathbb{C}),\|\cdot\|_1)\). These spaces are Banach, so there exist \[g_0\in C_0(\mathbb{R}^d;\mathbb{C}), \qquad h\in L^1(\mathbb{R}^d;\mathbb{C}),\] such that \[\|\psi_n-g_0\|_\infty\to0, \qquad \|\psi_n-h\|_1\to0.\] Uniform convergence gives \(\psi_n(x)\to g_0(x)\) for every \(x\). By \(L^1\)-convergence, a subsequence converges to \(h\) almost everywhere [72], Theorem 2.30. Hence \(g_0=h\) almost everywhere. We therefore identify \(h\) with the continuous representative \(g_0\), and obtain \[g_0\in L^1(\mathbb{R}^d;\mathbb{C}), \qquad \|\psi_n-g_0\|_1\to0.\]

For each multi-index \(\alpha\) with \(|\alpha|\le k\), the sequence \((\partial^\alpha\psi_n)\) is Cauchy in \(C_0(\mathbb{R}^d;\mathbb{C})\), because \[\|\partial^\alpha\psi_n-\partial^\alpha\psi_m\|_\infty \le \|\psi_n-\psi_m\|_{\Xi^k}.\] Let \(g_\alpha\in C_0(\mathbb{R}^d;\mathbb{C})\) denote its uniform limit: \[\|\partial^\alpha\psi_n-g_\alpha\|_\infty\to0.\]

It remains to identify \(g_\alpha\) with \(\partial^\alpha g_0\). If \(k=0\), there is nothing to prove. Suppose \(k\ge1\). Fix a multi-index \(\alpha\) with \(|\alpha|\le k-1\), a coordinate \(j\in\{1,\ldots,d\}\), a point \(x\in\mathbb{R}^d\), and \(t\in\mathbb{R}\). Here \(e_j\) denotes the \(j\)-th coordinate vector. For every \(n\), the fundamental theorem of calculus gives \[\partial^\alpha\psi_n(x+t e_j)-\partial^\alpha\psi_n(x) = \int_0^t \partial^{\alpha+e_j}\psi_n(x+s e_j)\,ds .\] Letting \(n\to\infty\) and using uniform convergence of the derivatives yields \[g_\alpha(x+t e_j)-g_\alpha(x) = \int_0^t g_{\alpha+e_j}(x+s e_j)\,ds .\] Since \(g_{\alpha+e_j}\) is continuous, this identity implies \[\partial_j g_\alpha(x)=g_{\alpha+e_j}(x).\] Applying this argument for all \(|\alpha|\le k-1\) and all \(j\), induction on \(|\alpha|\) gives \[g_0\in C^k(\mathbb{R}^d;\mathbb{C}), \qquad \partial^\alpha g_0=g_\alpha \quad\text{for all }|\alpha|\le k.\] Since \(g_\alpha\in C_0(\mathbb{R}^d;\mathbb{C})\) for every \(|\alpha|\le k\) and \(g_0\in L^1(\mathbb{R}^d;\mathbb{C})\), we have \(g_0\in\Xi^k\). Finally, \[\|\psi_n-g_0\|_{\Xi^k} = \max_{|\alpha|\le k} \|\partial^\alpha\psi_n-g_\alpha\|_\infty + \|\psi_n-g_0\|_1 \to0.\] Thus \(\Xi^k\) is complete.

Part (b): continuous inclusion of \(\mathcal{A}_V\) into \(\Xi^k\). Let \(f\in\mathcal{A}_V(\mathbb{R}^d)\). By definition of \(\mathcal{A}_V(\mathbb{R}^d)\), and using the unique representing measure, write \[f=f_V*\mu, \qquad \mu\in\mathcal{M}(\mathbb{R}^d).\]

First, \(f\in L^1(\mathbb{R}^d;\mathbb{C})\). Indeed, by Tonelli’s theorem applied to the total variation measure \(|\mu|\), \[\begin{align} \|f\|_1 &= \int_{\mathbb{R}^d} \left| \int_{\mathbb{R}^d} f_V(x-z)\,d\mu(z) \right|dx \\ &\le \int_{\mathbb{R}^d} \int_{\mathbb{R}^d} |f_V(x-z)|\,d|\mu|(z)\,dx \\ &= \int_{\mathbb{R}^d} \left( \int_{\mathbb{R}^d}|f_V(x-z)|\,dx \right)d|\mu|(z) \\ &= \|f_V\|_1\|\mu\|_{TV}. \end{align}\]

Next fix \(\alpha\) with \(|\alpha|\le k\), and define \[g_\alpha(x) \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} \partial^\alpha f_V(x-z)\,d\mu(z).\] This integral is well-defined because \(\partial^\alpha f_V\in C_0(\mathbb{R}^d;\mathbb{C})\subset L^\infty(\mathbb{R}^d;\mathbb{C})\), and \[|g_\alpha(x)| \le \|\partial^\alpha f_V\|_\infty\|\mu\|_{TV}.\]

We first show that \(g_\alpha\in C_0(\mathbb{R}^d;\mathbb{C})\). If \(x_n\to x\), then \[\partial^\alpha f_V(x_n-z)\to \partial^\alpha f_V(x-z) \qquad \text{for every }z\in\mathbb{R}^d,\] and \[|\partial^\alpha f_V(x_n-z)| \le \|\partial^\alpha f_V\|_\infty .\] The bound is \(|\mu|\)-integrable because \(|\mu|(\mathbb{R}^d)<\infty\). Dominated convergence gives \(g_\alpha(x_n)\to g_\alpha(x)\), so \(g_\alpha\) is continuous.

To prove that \(g_\alpha\) vanishes at infinity, set \[M_\alpha\mathrel{\mathop{:}}=\|\partial^\alpha f_V\|_\infty .\] Fix \(\varepsilon>0\). Since \(|\mu|\) is finite, choose a compact set \(K\subset\mathbb{R}^d\) such that \[|\mu|(K^c) < \frac{\varepsilon}{2(1+M_\alpha)}.\] Since \(\partial^\alpha f_V\in C_0(\mathbb{R}^d;\mathbb{C})\), choose \(R>0\) such that \[\|y\|_2>R \quad\Longrightarrow\quad |\partial^\alpha f_V(y)| < \frac{\varepsilon}{2(1+|\mu|(K))}.\] Because \(K\) is compact, there exists \(M>0\) such that \[\|x\|_2>M,\;z\in K \quad\Longrightarrow\quad \|x-z\|_2>R.\] For \(\|x\|_2>M\), \[\begin{align} |g_\alpha(x)| &\le \int_K |\partial^\alpha f_V(x-z)|\,d|\mu|(z) + \int_{K^c}|\partial^\alpha f_V(x-z)|\,d|\mu|(z) \\ &\le \frac{\varepsilon}{2(1+|\mu|(K))}\,|\mu|(K) + M_\alpha|\mu|(K^c) \\ &< \varepsilon . \end{align}\] Thus \(g_\alpha\in C_0(\mathbb{R}^d;\mathbb{C})\).

It remains to identify \(g_\alpha\) as \(\partial^\alpha f\). We argue by induction on \(|\alpha|\). For \(\alpha=0\), the identity \(g_0=f\) is the definition of \(f\). Suppose that, for some \(\alpha\) with \(|\alpha|\le k-1\), \[\partial^\alpha f(x) = \int_{\mathbb{R}^d} \partial^\alpha f_V(x-z)\,d\mu(z).\] Fix \(j\in\{1,\ldots,d\}\). For \(t\neq0\), \[\frac{\partial^\alpha f(x+t e_j)-\partial^\alpha f(x)}{t} = \int_{\mathbb{R}^d} \frac{ \partial^\alpha f_V(x+t e_j-z)-\partial^\alpha f_V(x-z) }{t} \,d\mu(z).\] For each \(z\), the integrand converges to \(\partial^{\alpha+e_j}f_V(x-z)\) as \(t\to0\). Moreover, the fundamental theorem of calculus gives \[\frac{ \partial^\alpha f_V(x+t e_j-z)-\partial^\alpha f_V(x-z) }{t} = \int_0^1 \partial^{\alpha+e_j}f_V(x+s t e_j-z)\,ds,\] and therefore \[\left| \frac{ \partial^\alpha f_V(x+t e_j-z)-\partial^\alpha f_V(x-z) }{t} \right| \le \|\partial^{\alpha+e_j}f_V\|_\infty .\] The right-hand side is \(|\mu|\)-integrable. Dominated convergence yields \[\partial^{\alpha+e_j}f(x) = \int_{\mathbb{R}^d} \partial^{\alpha+e_j}f_V(x-z)\,d\mu(z) = g_{\alpha+e_j}(x).\] By induction, \[\partial^\alpha f=g_\alpha\in C_0(\mathbb{R}^d;\mathbb{C}) \qquad \text{for all }|\alpha|\le k.\] Together with the \(L^1\) bound above, this proves \[f\in\Xi^k(\mathbb{R}^d;\mathbb{C}).\]

The same estimates give the continuity of the inclusion. If \(\mu=\mathcal{K}_V^{-1}[f]\), then \[\|f\|_1 \le \|f_V\|_1\|\mu\|_{TV},\] and, for every \(|\alpha|\le k\), \[\|\partial^\alpha f\|_\infty \le \|\partial^\alpha f_V\|_\infty\|\mu\|_{TV}.\] Hence \[\begin{align} \|f\|_{\Xi^k} &= \max_{|\alpha|\le k}\|\partial^\alpha f\|_\infty + \|f\|_1 \\ &\le \left( \max_{|\alpha|\le k}\|\partial^\alpha f_V\|_\infty + \|f_V\|_1 \right)\|\mu\|_{TV}. \end{align}\] Since \(\|\mu\|_{TV}=\|f\|_{\mathcal{A}_V}\), we obtain \[\|f\|_{\Xi^k} \le C_{V,k}\|f\|_{\mathcal{A}_V}, \qquad C_{V,k} \mathrel{\mathop{:}}= \max_{|\alpha|\le k}\|\partial^\alpha f_V\|_\infty + \|f_V\|_1 .\] Thus the embedding \[\mathcal{A}_V(\mathbb{R}^d)\hookrightarrow \Xi^k(\mathbb{R}^d;\mathbb{C})\] is continuous.

Part (c): continuous and dense inclusion of the Schwartz space. We first prove continuity of the inclusion \[\mathscr S(\mathbb{R}^d)\hookrightarrow \Xi^k(\mathbb{R}^d;\mathbb{C}).\] For \(\varphi\in\mathscr S(\mathbb{R}^d)\), define the Schwartz seminorm \[Q_{d,k}(\varphi) \mathrel{\mathop{:}}= \max_{|\alpha|\le k} \sup_{x\in\mathbb{R}^d} (1+\|x\|_2)^{d+1}|\partial^\alpha\varphi(x)|.\] Then \[\max_{|\alpha|\le k}\|\partial^\alpha\varphi\|_\infty \le Q_{d,k}(\varphi),\] and \[\begin{align} \|\varphi\|_1 &= \int_{\mathbb{R}^d} (1+\|x\|_2)^{-d-1} (1+\|x\|_2)^{d+1} |\varphi(x)|\,dx \\ &\le \left( \int_{\mathbb{R}^d} (1+\|x\|_2)^{-d-1}\,dx \right) Q_{d,k}(\varphi). \end{align}\] The integral is finite. Hence \[\|\varphi\|_{\Xi^k} \le C_{d,k}Q_{d,k}(\varphi),\] which proves continuity of the inclusion.

It remains to prove density. Let \(\psi\in\Xi^k(\mathbb{R}^d;\mathbb{C})\). Choose \(\chi\in C_c^\infty(\mathbb{R}^d)\) such that \(0\le\chi\le1\), \(\chi\equiv1\) on \(B(0,1)\), and \(\chi\equiv0\) outside \(B(0,2)\). For \(R\ge1\), define \[\chi_R(x)\mathrel{\mathop{:}}=\chi(x/R), \qquad \psi_R(x)\mathrel{\mathop{:}}=\chi_R(x)\psi(x).\] Then \(\psi_R\in C_c^k(\mathbb{R}^d;\mathbb{C})\).

We first show that \(\psi_R\to\psi\) in \(\Xi^k\). Since \(\chi_R(x)\to1\) for every \(x\) and \[|(\chi_R(x)-1)\psi(x)|\le |\psi(x)|,\] dominated convergence gives \[\|\psi_R-\psi\|_1\to0.\] Now fix \(\alpha\) with \(|\alpha|\le k\). By Leibniz’s rule, \[\partial^\alpha(\psi_R-\psi) = (\chi_R-1)\partial^\alpha\psi + \sum_{0<\beta\le\alpha} {\alpha\choose\beta} (\partial^\beta\chi_R)\partial^{\alpha-\beta}\psi .\] Because \(\chi_R=1\) on \(B(0,R)\) and \(\partial^\alpha\psi\in C_0(\mathbb{R}^d;\mathbb{C})\), \[\|(\chi_R-1)\partial^\alpha\psi\|_\infty\to0.\] For \(0<\beta\le\alpha\), \[\partial^\beta\chi_R(x) = R^{-|\beta|}(\partial^\beta\chi)(x/R),\] and \[\operatorname{supp}(\partial^\beta\chi_R) \subset \{x\in\mathbb{R}^d:R\le \|x\|_2\le 2R\}.\] Thus \[\|(\partial^\beta\chi_R)\partial^{\alpha-\beta}\psi\|_\infty \le R^{-|\beta|} \|\partial^\beta\chi\|_\infty \sup_{\|x\|_2\ge R} |\partial^{\alpha-\beta}\psi(x)|.\] Since \(\partial^{\alpha-\beta}\psi\in C_0(\mathbb{R}^d;\mathbb{C})\), the right-hand side tends to zero. Therefore \[\max_{|\alpha|\le k} \|\partial^\alpha(\psi_R-\psi)\|_\infty \to0,\] and hence \[\|\psi_R-\psi\|_{\Xi^k}\to0.\]

Now choose a standard compactly supported mollifier \(\rho\in C_c^\infty(\mathbb{R}^d)\) with \(\int\rho=1\), and set \[\rho_\varepsilon(x) \mathrel{\mathop{:}}= \varepsilon^{-d}\rho(x/\varepsilon), \qquad \psi_{R,\varepsilon} \mathrel{\mathop{:}}= \rho_\varepsilon*\psi_R .\] For fixed \(R\), we have \[\psi_{R,\varepsilon}\in C_c^\infty(\mathbb{R}^d)\subset\mathscr S(\mathbb{R}^d).\] Standard properties of mollifiers give, for every \(|\alpha|\le k\), \[\partial^\alpha\psi_{R,\varepsilon} = \rho_\varepsilon*\partial^\alpha\psi_R,\] and \[\|\psi_{R,\varepsilon}-\psi_R\|_1\to0, \qquad \|\partial^\alpha\psi_{R,\varepsilon} -\partial^\alpha\psi_R\|_\infty\to0 \quad (|\alpha|\le k),\] as \(\varepsilon\downarrow0\); see [72], Propositions 8.10 and 8.14. Hence \[\|\psi_{R,\varepsilon}-\psi_R\|_{\Xi^k}\to0 \qquad (\varepsilon\downarrow0).\]

For each \(n\), choose \(R_n\) such that \[\|\psi_{R_n}-\psi\|_{\Xi^k}<\frac{1}{2n},\] and then choose \(\varepsilon_n>0\) such that \[\|\psi_{R_n,\varepsilon_n}-\psi_{R_n}\|_{\Xi^k}<\frac{1}{2n}.\] The functions \[\varphi_n\mathrel{\mathop{:}}=\psi_{R_n,\varepsilon_n}\] belong to \(\mathscr S(\mathbb{R}^d)\), and \[\|\varphi_n-\psi\|_{\Xi^k}\le \frac{1}{n}.\] Thus \(\mathscr S(\mathbb{R}^d)\) is dense in \(\Xi^k(\mathbb{R}^d;\mathbb{C})\). ◻

1.0.1.2.5 Proof of Theorem 2

The proof uses one auxiliary fact about translations on \(\Xi^k\) discussed in the next Lemma:

Lemma 3 (Translations on \(\Xi^k\) and Bochner representation of convolution). For \(x\in\mathbb{R}^d\), define \[(\tau_x f)(t) \mathrel{\mathop{:}}= f(t-x), \qquad t\in\mathbb{R}^d.\] Then the following statements hold.

  1. The family \((\tau_x)_{x\in\mathbb{R}^d}\) is a strongly continuous group of linear isometries on \(\Xi^k(\mathbb{R}^d;\mathbb{C})\). In particular, for each \(f\in\Xi^k(\mathbb{R}^d;\mathbb{C})\), the orbit map \[x\longmapsto \tau_x f\] is bounded and continuous from \(\mathbb{R}^d\) into \(\Xi^k(\mathbb{R}^d;\mathbb{C})\).

  2. Under Assumption 4, for every \(\mu\in\mathcal{M}(\mathbb{R}^d)\), the map \(x\mapsto \tau_x f_V\) is Bochner integrable with respect to \(\mu\), and \[f_V*\mu = \int_{\mathbb{R}^d}\tau_x f_V\,d\mu(x) \qquad \text{in } \Xi^k(\mathbb{R}^d;\mathbb{C}).\]

Proof. We first prove part (a). Each \(\tau_x\) is linear. Moreover, for every multi-index \(\alpha\) with \(|\alpha|\le k\), \[\partial^\alpha(\tau_x\psi) = \tau_x(\partial^\alpha\psi).\] Thus translation preserves both the derivative sup norms and the \(L^1\)-norm: \[\|\partial^\alpha(\tau_x\psi)\|_\infty = \|\partial^\alpha\psi\|_\infty, \qquad \|\tau_x\psi\|_1 = \|\psi\|_1.\] Therefore \[\|\tau_x\psi\|_{\Xi^k} = \|\psi\|_{\Xi^k}, \qquad \psi\in\Xi^k(\mathbb{R}^d;\mathbb{C}).\] Each \(\tau_x\) is an isometry. Since \[\tau_0=\mathrm{Id}, \qquad \tau_x\tau_y=\tau_{x+y},\] the family \((\tau_x)_{x\in\mathbb{R}^d}\) is a group.

It remains to prove strong continuity. Fix \(f\in\Xi^k(\mathbb{R}^d;\mathbb{C})\). At the origin, \[\|\tau_x f-f\|_{\Xi^k} = \max_{|\alpha|\le k} \|\tau_x(\partial^\alpha f)-\partial^\alpha f\|_\infty + \|\tau_x f-f\|_1.\] The \(L^1\)-term tends to zero as \(x\to0\) by continuity of translations in \(L^1\); see [72], Proposition 8.5. For each \(|\alpha|\le k\), \(\partial^\alpha f\in C_0(\mathbb{R}^d;\mathbb{C})\), hence \(\partial^\alpha f\) is uniformly continuous. Therefore \[\|\tau_x(\partial^\alpha f)-\partial^\alpha f\|_\infty \to0 \qquad (x\to0).\] Thus \[\|\tau_x f-f\|_{\Xi^k}\to0 \qquad (x\to0).\] For any \(x_0\in\mathbb{R}^d\), \[\|\tau_x f-\tau_{x_0}f\|_{\Xi^k} = \|\tau_{x-x_0}f-f\|_{\Xi^k} \to0 \qquad (x\to x_0),\] because \(\tau_{x_0}\) is an isometry. This proves part (a).

We now prove part (b). Assumption 4 implies that \(\partial^\alpha f_V\in C_0(\mathbb{R}^d;\mathbb{C})\) for all \(|\alpha|\le k\). Since \(f_V\) is a density, \(f_V\in L^1(\mathbb{R}^d)\). Hence \[f_V\in\Xi^k(\mathbb{R}^d;\mathbb{C}).\] Define \[\Phi:\mathbb{R}^d\to\Xi^k(\mathbb{R}^d;\mathbb{C}), \qquad \Phi(x)\mathrel{\mathop{:}}=\tau_x f_V.\] By part (a), \(\Phi\) is bounded and continuous. Since \(\mathbb{R}^d\) is separable, \(\Phi\) has separable range and is strongly measurable with respect to \(|\mu|\). Also, \[\int_{\mathbb{R}^d}\|\Phi(x)\|_{\Xi^k}\,d|\mu|(x) = \|f_V\|_{\Xi^k}\,|\mu|(\mathbb{R}^d) <\infty.\] Thus \(\Phi\) is Bochner integrable with respect to \(|\mu|\).

Since \(\mu\) is a finite complex measure, there exists a measurable function \(\sigma_\mu\), with \(|\sigma_\mu|=1\) \(|\mu|\)-a.e., such that \[d\mu=\sigma_\mu\,d|\mu|;\] see [54], Theorem 6.12. We define \[\int_{\mathbb{R}^d}\Phi(x)\,d\mu(x) \mathrel{\mathop{:}}= \int_{\mathbb{R}^d}\sigma_\mu(x)\Phi(x)\,d|\mu|(x).\] Set \[F \mathrel{\mathop{:}}= \int_{\mathbb{R}^d}\tau_x f_V\,d\mu(x) \in \Xi^k(\mathbb{R}^d;\mathbb{C}).\]

We identify \(F\). For \(|\alpha|\le k\), the map \[J_\alpha:\Xi^k(\mathbb{R}^d;\mathbb{C})\to C_0(\mathbb{R}^d;\mathbb{C}), \qquad J_\alpha(h)\mathrel{\mathop{:}}=\partial^\alpha h,\] is bounded and linear. Bounded linear maps commute with Bochner integration; see [73], Theorem 3.1.7. Hence \[\partial^\alpha F = \int_{\mathbb{R}^d}\tau_x(\partial^\alpha f_V)\,d\mu(x) \qquad \text{in } C_0(\mathbb{R}^d;\mathbb{C}).\] Evaluating at \(t\in\mathbb{R}^d\) gives \[\partial^\alpha F(t) = \int_{\mathbb{R}^d} \partial^\alpha f_V(t-x)\,d\mu(x).\] Taking \(\alpha=0\), we obtain \[F(t) = \int_{\mathbb{R}^d}f_V(t-x)\,d\mu(x) = (f_V*\mu)(t).\] Therefore \[f_V*\mu = \int_{\mathbb{R}^d}\tau_x f_V\,d\mu(x) \qquad \text{in } \Xi^k(\mathbb{R}^d;\mathbb{C}).\] This proves part (b). ◻

Proof of Theorem 2. Set \[\lambda\mathrel{\mathop{:}}=\lambda_{g,V,y}, \qquad Q\mathrel{\mathop{:}}=\mathcal{Q}_{g,V,y}, \qquad L_Q\mathrel{\mathop{:}}=\mathcal{F}^{-1}\{\mathcal{I}_Q\}.\] By assumption (i) and Lemma 2, \[\mathcal{I}_Q\in\mathscr S'(\mathbb{R}^d).\] Hence \[L_Q\in\mathscr S'(\mathbb{R}^d).\] Assumption (ii) gives \[\label{eq:master-fourier-bound} |L_Q[\psi]| \le C\|\psi\|_{\Xi^k}, \qquad \psi\in\mathscr S(\mathbb{R}^d).\tag{4}\] Thus \(L_Q\) is continuous on \(\mathscr S(\mathbb{R}^d)\) when \(\mathscr S(\mathbb{R}^d)\) is equipped with the \(\Xi^k\)-norm.

By Lemma 1(c), \(\mathscr S(\mathbb{R}^d)\) is dense in \(\Xi^k(\mathbb{R}^d;\mathbb{C})\). Therefore 4 extends \(L_Q\) uniquely to a continuous linear functional \[\overline{L}_Q\in \bigl(\Xi^k(\mathbb{R}^d;\mathbb{C})\bigr)'.\] By Lemma 1(b), \[\mathcal{A}_V(\mathbb{R}^d) \subset \Xi^k(\mathbb{R}^d;\mathbb{C}),\] so the restriction \[\overline{L}_Q|_{\mathcal{A}_V(\mathbb{R}^d)}\] is well-defined. We prove that this restriction is \(\mathcal{T}_{g,V,y}\).

For \(\psi\in\mathscr S(\mathbb{R}^d)\), the definition of the inverse Fourier transform on tempered distributions gives \[\label{eq:master-fourier-action} \begin{align} L_Q[\psi] &= \mathcal{I}_Q[\psi^\sharp] \\ &= \int_{\mathbb{R}^d}Q(\omega)\psi^\sharp(\omega)\,d\omega \\ &= \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d}Q(\omega)\widetilde{\psi}(-\omega)\,d\omega, \end{align}\tag{5}\] where \[\psi^\sharp(\omega) = (2\pi)^{-d}\widetilde{\psi}(-\omega).\]

Define \[\Psi(x) \mathrel{\mathop{:}}= \overline{L}_Q[\tau_x f_V], \qquad x\in\mathbb{R}^d.\] By Lemma 3(a), the map \(x\mapsto\tau_x f_V\) is bounded and continuous into \(\Xi^k(\mathbb{R}^d;\mathbb{C})\). Since \(\overline{L}_Q\) is continuous, \(\Psi\) is bounded and continuous.

We next identify \(\Psi\). Let \(\eta\in\mathscr S(\mathbb{R}^d)\), and let \(\mu_\eta\in\mathcal{M}(\mathbb{R}^d)\) be the finite complex measure \[d\mu_\eta(x)=\eta(x)\,dx.\] By Lemma 3(b), \[f_V*\eta = \int_{\mathbb{R}^d}\eta(x)\tau_x f_V\,dx \qquad \text{in } \Xi^k(\mathbb{R}^d;\mathbb{C}).\] Applying \(\overline{L}_Q\) and using again [73], Theorem 3.1.7, gives \[\label{eq:master-pairing-Psi} \int_{\mathbb{R}^d}\Psi(x)\eta(x)\,dx = \overline{L}_Q[f_V*\eta].\tag{6}\]

Choose \((u_n)_{n\ge1}\subset\mathscr S(\mathbb{R}^d)\) such that \[u_n\to f_V \qquad \text{in } \Xi^k(\mathbb{R}^d;\mathbb{C}),\] which is possible by Lemma 1(c). We use the elementary bound \[\label{eq:master-convolution-estimate} \|\zeta*\eta\|_{\Xi^k} \le \|\zeta\|_{\Xi^k}\|\eta\|_1, \qquad \zeta\in\Xi^k(\mathbb{R}^d;\mathbb{C}),\quad \eta\in L^1(\mathbb{R}^d;\mathbb{C}).\tag{7}\] Indeed, for every \(|\alpha|\le k\), \[\partial^\alpha(\zeta*\eta) = (\partial^\alpha\zeta)*\eta,\] and therefore \[\|\partial^\alpha(\zeta*\eta)\|_\infty \le \|\partial^\alpha\zeta\|_\infty\|\eta\|_1.\] Also, \[\|\zeta*\eta\|_1 \le \|\zeta\|_1\|\eta\|_1.\] Combining these inequalities proves 7 .

Applying 7 to \(\zeta=u_n-f_V\) gives \[u_n*\eta\to f_V*\eta \qquad \text{in } \Xi^k(\mathbb{R}^d;\mathbb{C}).\] Since \(\overline{L}_Q\) is continuous, \[\label{eq:master-limit-extension} \overline{L}_Q[f_V*\eta] = \lim_{n\to\infty}\overline{L}_Q[u_n*\eta].\tag{8}\] Moreover, \(u_n*\eta\in\mathscr S(\mathbb{R}^d)\), because the Schwartz space is closed under convolution; see [74], Chapter 5, Proposition 1.11. Hence \(\overline{L}_Q[u_n*\eta]=L_Q[u_n*\eta]\). By 5 , \[\label{eq:master-convolution-fourier} L_Q[u_n*\eta] = \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} Q(\omega)\widetilde{u}_n(-\omega)\widetilde{\eta}(-\omega)\,d\omega.\tag{9}\]

Since \(u_n\to f_V\) in \(L^1(\mathbb{R}^d;\mathbb{C})\), \[\sup_{\omega\in\mathbb{R}^d} |\widetilde{u}_n(\omega)-\varphi_V(\omega)| \le \|u_n-f_V\|_1 \to0.\] Thus \(\widetilde{u}_n\to\varphi_V\) uniformly on \(\mathbb{R}^d\). Also, \[\sup_{n\ge1}\|\widetilde{u}_n\|_\infty \le \sup_{n\ge1}\|u_n\|_1 <\infty.\]

Let \(N\) be the integer from assumption (i). Since \(\widetilde{\eta}\in\mathscr S(\mathbb{R}^d)\), there exists \(C_{\eta,N}>0\) such that \[|\widetilde{\eta}(-\omega)| \le C_{\eta,N}(1+\|\omega\|_2)^{-N}.\] Hence \[|Q(\omega)\widetilde{\eta}(-\omega)| \le C_{\eta,N} \frac{|Q(\omega)|}{(1+\|\omega\|_2)^N},\] and the right-hand side is integrable by assumption (i). Therefore \[|Q(\omega)\widetilde{u}_n(-\omega)\widetilde{\eta}(-\omega)| \le \left(\sup_{m\ge1}\|\widetilde{u}_m\|_\infty\right) |Q(\omega)\widetilde{\eta}(-\omega)|.\] Dominated convergence in 9 yields \[\label{eq:master-fVeta-fourier} \overline{L}_Q[f_V*\eta] = \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} Q(\omega)\varphi_V(-\omega)\widetilde{\eta}(-\omega)\,d\omega.\tag{10}\]

Since \(|\varphi_V|\le1\), assumption (i) and Lemma 2 imply that \[\mathcal{I}_{\omega\mapsto Q(\omega)\varphi_V(-\omega)} \in \mathscr S'(\mathbb{R}^d).\] By 10 and the definition of the inverse Fourier transform on \(\mathscr S'(\mathbb{R}^d)\), \[\overline{L}_Q[f_V*\eta] = \mathcal{F}^{-1} \left\{ \mathcal{I}_{\omega\mapsto Q(\omega)\varphi_V(-\omega)} \right\}[\eta].\] Assumption (iii) gives \[\mathcal{F}^{-1} \left\{ \mathcal{I}_{\omega\mapsto Q(\omega)\varphi_V(-\omega)} \right\} = \mathcal{I}_\lambda \qquad \text{in } \mathscr S'(\mathbb{R}^d).\] Therefore \[\overline{L}_Q[f_V*\eta] = \mathcal{I}_\lambda[\eta] = \int_{\mathbb{R}^d}\lambda(x)\eta(x)\,dx, \qquad \eta\in\mathscr S(\mathbb{R}^d).\]

Combining this identity with 6 , we obtain \[\int_{\mathbb{R}^d}\Psi(x)\eta(x)\,dx = \int_{\mathbb{R}^d}\lambda(x)\eta(x)\,dx, \qquad \eta\in\mathscr S(\mathbb{R}^d).\] Thus \(\Psi-\lambda=0\) in \(\mathscr S'(\mathbb{R}^d)\). Since \(\Psi\) is continuous and \(\lambda\in C_0(\mathbb{R}^d;\mathbb{C})\), both functions are locally integrable. The distributional equality implies \(\Psi=\lambda\) Lebesgue-a.e. Since both functions are continuous, \[\Psi(x)=\lambda(x), \qquad x\in\mathbb{R}^d.\]

We now identify the restriction of \(\overline{L}_Q\) to \(\mathcal{A}_V(\mathbb{R}^d)\). Let \(f\in\mathcal{A}_V(\mathbb{R}^d)\), and set \[\mu_f\mathrel{\mathop{:}}=\mathcal{K}_V^{-1}[f].\] Then \[f=f_V*\mu_f.\] By Lemma 3(b), \[f = \int_{\mathbb{R}^d}\tau_x f_V\,d\mu_f(x) \qquad \text{in } \Xi^k(\mathbb{R}^d;\mathbb{C}).\] Applying \(\overline{L}_Q\) and using Bochner integration once more, \[\begin{align} \overline{L}_Q[f] &= \int_{\mathbb{R}^d} \overline{L}_Q[\tau_x f_V]\,d\mu_f(x) \\ &= \int_{\mathbb{R}^d}\Psi(x)\,d\mu_f(x) \\ &= \int_{\mathbb{R}^d}\lambda(x)\,d\mu_f(x) \\ &= \mathcal{T}_{g,V,y}[f]. \end{align}\] Hence \[\overline{L}_Q|_{\mathcal{A}_V(\mathbb{R}^d)} = \mathcal{T}_{g,V,y}.\]

Finally, let \(f\in\mathcal{A}_V(\mathbb{R}^d)\), and let \((f_n)_{n\ge1}\subset\mathscr S(\mathbb{R}^d)\) satisfy \[\|f_n-f\|_{\Xi^k}\to0.\] Since \(\overline{L}_Q\) extends \(L_Q\) and is continuous on \(\Xi^k\), \[L_Q[f_n] = \overline{L}_Q[f_n] \to \overline{L}_Q[f] = \mathcal{T}_{g,V,y}[f].\] Using 5 with \(\psi=f_n\), this is the same as \[\frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} Q(\omega)\widetilde{f}_n(-\omega)\,d\omega \to \mathcal{T}_{g,V,y}[f].\] The limit is therefore independent of the approximating sequence. ◻

1.0.1.2.6 Proof of Proposition 3

Proof. Write \[\lambda_n\mathrel{\mathop{:}}=\lambda_{n,g,V,y}, \qquad \lambda\mathrel{\mathop{:}}=\lambda_{g,V,y}, \qquad \mathcal{T}_n\mathrel{\mathop{:}}=\mathcal{T}_{n,g,V,y}.\] For each \(n\), \(\lambda_n\in C_0(\mathbb{R}^d;\mathbb{C})\). Hence Theorem 1 gives a unique continuous linear functional \[\mathcal{T}_n\in\mathcal{A}_V'(\mathbb{R}^d)\] such that \[\mathcal{T}_n[f_V*\mu] = \int_{\mathbb{R}^d}\lambda_n(x)\,d\mu(x), \qquad \mu\in\mathcal{M}(\mathbb{R}^d).\]

We now construct the limiting functional. By assumption, \[\lambda_n(x)\to\lambda(x), \qquad x\in\mathbb{R}^d,\] and \[M_\lambda \mathrel{\mathop{:}}= \sup_{n\ge1}\|\lambda_n\|_\infty <\infty .\] Since \(\lambda\) is the pointwise limit of continuous functions, it is Borel measurable. Moreover, \[\|\lambda\|_\infty\le M_\lambda .\]

For \(f\in\mathcal{A}_V(\mathbb{R}^d)\), let \[\mu_f\mathrel{\mathop{:}}=\mathcal{K}_V^{-1}[f].\] The measure \(\mu_f\) is well-defined and unique by Proposition 2. Define \[\mathcal{T}_{g,V,y}[f] \mathrel{\mathop{:}}= \int_{\mathbb{R}^d}\lambda(x)\,d\mu_f(x).\] This map is linear because \(f\mapsto\mu_f\) is linear. It is also continuous: \[|\mathcal{T}_{g,V,y}[f]| \le \|\lambda\|_\infty\|\mu_f\|_{TV} = \|\lambda\|_\infty\|f\|_{\mathcal{A}_V}.\] Therefore \[\mathcal{T}_{g,V,y}\in\mathcal{A}_V'(\mathbb{R}^d).\]

This functional is the unique continuous linear functional with the displayed integral representation. Indeed, if \(S\in\mathcal{A}_V'(\mathbb{R}^d)\) satisfies \[S[f_V*\mu] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu(x), \qquad \mu\in\mathcal{M}(\mathbb{R}^d),\] then, for any \(f\in\mathcal{A}_V(\mathbb{R}^d)\), \[S[f] = S[f_V*\mu_f] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu_f(x) = \mathcal{T}_{g,V,y}[f].\] Hence \(S=\mathcal{T}_{g,V,y}\).

It remains to prove convergence. Fix \(f\in\mathcal{A}_V(\mathbb{R}^d)\), and write \(\mu_f=\mathcal{K}_V^{-1}[f]\). Then \[\mathcal{T}_n[f] = \int_{\mathbb{R}^d}\lambda_n(x)\,d\mu_f(x), \qquad \mathcal{T}_{g,V,y}[f] = \int_{\mathbb{R}^d}\lambda(x)\,d\mu_f(x).\] Since \[\lambda_n(x)-\lambda(x)\to0 \qquad \text{for every }x\in\mathbb{R}^d,\] and \[|\lambda_n(x)-\lambda(x)| \le 2M_\lambda, \qquad x\in\mathbb{R}^d,\] the dominated convergence theorem, applied with respect to the finite measure \(|\mu_f|\), gives \[\int_{\mathbb{R}^d} |\lambda_n(x)-\lambda(x)|\,d|\mu_f|(x) \to0.\] Consequently, \[\begin{align} |\mathcal{T}_n[f]-\mathcal{T}_{g,V,y}[f]| &= \left| \int_{\mathbb{R}^d} \{\lambda_n(x)-\lambda(x)\}\,d\mu_f(x) \right| \\ &\le \int_{\mathbb{R}^d} |\lambda_n(x)-\lambda(x)|\,d|\mu_f|(x) \to0 . \end{align}\] Thus \[\mathcal{T}_n[f]\to\mathcal{T}_{g,V,y}[f], \qquad f\in\mathcal{A}_V(\mathbb{R}^d).\]

Now suppose that \((Y,X,V)\) also satisfies Assumption 1. By Proposition 1, \[f_Y = f_V*P_X = \mathcal{K}_V[P_X],\] so \(f_Y\in\mathcal{A}_V(\mathbb{R}^d)\). Applying the preceding convergence result with \(f=f_Y\) yields \[\mathcal{T}_{g,V,y}[f_Y] = \lim_{n\to\infty}\mathcal{T}_{n,g,V,y}[f_Y].\]

Finally, by the definition of \(\lambda_{g,V,y}\), \[\mathcal{T}_{g,V,y}[f_Y] = \int_{\mathbb{R}^d}\lambda_{g,V,y}(x)\,dP_X(x) = \int_{\mathbb{R}^d}g(x)f_V(y-x)\,dP_X(x).\] Therefore, whenever \(f_Y(y)>0\), the ratio formula 3 gives \[\mathbb{E}[g(X)\mid Y=y] = \frac{ \int_{\mathbb{R}^d}g(x)f_V(y-x)\,dP_X(x) }{ f_Y(y) } = \frac{\mathcal{T}_{g,V,y}[f_Y]}{f_Y(y)} = \lim_{n\to\infty} \frac{\mathcal{T}_{n,g,V,y}[f_Y]}{f_Y(y)}.\] This proves the approximation formula. ◻

1.0.1.2.7 Proof of Proposition 4

Proof. Set \[Q(\omega)\mathrel{\mathop{:}}=\mathcal{Q}_{g,V,y}(\omega), \qquad R(\omega)\mathrel{\mathop{:}}= \sum_{|\alpha|\le k}(i\omega)^\alpha \varphi_{\mu_\alpha}(\omega).\] By assumption, \(Q=R\) Lebesgue-a.e. Hence \[\mathcal{I}_Q=\mathcal{I}_R \qquad \text{on } \mathscr S(\mathbb{R}^d).\]

Step 1: temperedness. For each \(|\alpha|\le k\), the Fourier–Stieltjes transform of \(\mu_\alpha\) is bounded: \[|\varphi_{\mu_\alpha}(\omega)| = \left| \int_{\mathbb{R}^d}e^{i\omega^\top z}\,d\mu_\alpha(z) \right| \le \|\mu_\alpha\|_{TV}, \qquad \omega\in\mathbb{R}^d.\] Therefore there is a finite constant \(C>0\) such that \[|R(\omega)| \le \sum_{|\alpha|\le k} |\omega^\alpha|\|\mu_\alpha\|_{TV} \le C(1+\|\omega\|_2)^k .\] Since \(Q=R\) Lebesgue-a.e., the same polynomial bound holds for \(Q\) after changing \(Q\) on a null set. Thus, for any integer \(N>k+d\), \[\int_{\mathbb{R}^d} \frac{|Q(\omega)|}{(1+\|\omega\|_2)^N}\,d\omega \le C \int_{\mathbb{R}^d} (1+\|\omega\|_2)^{k-N}\,d\omega <\infty.\] Lemma 2 gives \[\mathcal{I}_Q\in\mathscr S'(\mathbb{R}^d).\]

Step 2: inverse Fourier transform on the Schwartz class. Let \(\psi\in\mathscr S(\mathbb{R}^d)\). Since \[\psi^\sharp(\omega) = (2\pi)^{-d}\widetilde{\psi}(-\omega)\] belongs to \(\mathscr S(\mathbb{R}^d)\), we have \[\int_{\mathbb{R}^d} |\omega^\alpha\psi^\sharp(\omega)|\,d\omega <\infty \qquad (|\alpha|\le k).\] Because each \(\mu_\alpha\) is finite, Fubini’s theorem applies: \[\int_{\mathbb{R}^d} \int_{\mathbb{R}^d} |\omega^\alpha\psi^\sharp(\omega)| \,d\omega\,d|\mu_\alpha|(z) <\infty .\] Using \(Q=R\) a.e., \[\begin{align} \mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi] &= \mathcal{I}_Q[\psi^\sharp] \\ &= \int_{\mathbb{R}^d}Q(\omega)\psi^\sharp(\omega)\,d\omega \\ &= \sum_{|\alpha|\le k} \int_{\mathbb{R}^d} (i\omega)^\alpha \varphi_{\mu_\alpha}(\omega) \psi^\sharp(\omega)\,d\omega \\ &= \sum_{|\alpha|\le k} \int_{\mathbb{R}^d} \left[ \int_{\mathbb{R}^d} (i\omega)^\alpha e^{i\omega^\top z} \psi^\sharp(\omega)\,d\omega \right]d\mu_\alpha(z). \end{align}\] By Fourier inversion under our convention, \[\psi(z) = \int_{\mathbb{R}^d} e^{i\omega^\top z}\psi^\sharp(\omega)\,d\omega .\] Differentiating under the integral sign gives, for every \(|\alpha|\le k\), \[\partial^\alpha\psi(z) = \int_{\mathbb{R}^d} (i\omega)^\alpha e^{i\omega^\top z} \psi^\sharp(\omega)\,d\omega .\] Therefore \[\mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi] = \sum_{|\alpha|\le k} \int_{\mathbb{R}^d} \partial^\alpha\psi(z)\,d\mu_\alpha(z), \qquad \psi\in\mathscr S(\mathbb{R}^d).\]

Step 3: \(\Xi^k\)-continuity. Define, for \(\psi\in\Xi^k(\mathbb{R}^d;\mathbb{C})\), \[L[\psi] \mathrel{\mathop{:}}= \sum_{|\alpha|\le k} \int_{\mathbb{R}^d} \partial^\alpha\psi(z)\,d\mu_\alpha(z).\] This is well-defined because \(\partial^\alpha\psi\in C_0(\mathbb{R}^d;\mathbb{C})\) for every \(|\alpha|\le k\). Moreover, \[\begin{align} |L[\psi]| &\le \sum_{|\alpha|\le k} \left| \int_{\mathbb{R}^d} \partial^\alpha\psi(z)\,d\mu_\alpha(z) \right| \\ &\le \sum_{|\alpha|\le k} \|\partial^\alpha\psi\|_\infty \|\mu_\alpha\|_{TV} \\ &\le \left( \sum_{|\alpha|\le k} \|\mu_\alpha\|_{TV} \right) \|\psi\|_{\Xi^k}. \end{align}\] Thus \(L\) is a continuous linear functional on \(\Xi^k(\mathbb{R}^d;\mathbb{C})\). Step 2 shows that \[\mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi] = L[\psi], \qquad \psi\in\mathscr S(\mathbb{R}^d).\] Hence condition (ii) of Theorem 2 holds.

The assumptions of the proposition give the standing hypotheses of Theorem 2. Moreover, Step 1 verifies condition (i), Step 3 verifies condition (ii), and the assumption that \(Q\) is a Fourier-domain representer for \(\lambda_{g,V,y}\) gives condition (iii). Applying Theorem 2, we obtain, for every \(f\in\mathcal{A}_V(\mathbb{R}^d)\), \[\mathcal{T}_{g,V,y}[f] = \lim_{n\to\infty} \mathcal{F}^{-1}\{\mathcal{I}_Q\}[f_n],\] whenever \((f_n)_{n\ge1}\subset\mathscr S(\mathbb{R}^d)\) satisfies \[\|f_n-f\|_{\Xi^k}\to0.\] Since \(L\) is continuous on \(\Xi^k(\mathbb{R}^d;\mathbb{C})\), Step 2 gives \[\lim_{n\to\infty} \mathcal{F}^{-1}\{\mathcal{I}_Q\}[f_n] = \lim_{n\to\infty}L[f_n] = L[f].\] Therefore \[\mathcal{T}_{g,V,y}[f] = \sum_{|\alpha|\le k} \int_{\mathbb{R}^d} \partial^\alpha f(z)\,d\mu_\alpha(z), \qquad f\in\mathcal{A}_V(\mathbb{R}^d).\]

Finally, under Assumption 1, Proposition 1 gives \[f_Y = f_V*P_X \in \mathcal{A}_V(\mathbb{R}^d).\] Taking \(f=f_Y\) in the preceding display yields \[\mathcal{T}_{g,V,y}[f_Y] = \sum_{|\alpha|\le k} \int_{\mathbb{R}^d} \partial^\alpha f_Y(z)\,d\mu_\alpha(z).\] By the ratio formula 3 , whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{\mathcal{T}_{g,V,y}[f_Y]}{f_Y(y)} = \frac{ \displaystyle \sum_{|\alpha|\le k} \int_{\mathbb{R}^d} \partial^\alpha f_Y(z)\,d\mu_\alpha(z) }{ f_Y(y) }.\] This is the stated posterior representation. ◻

1.0.1.2.8 Proof of Proposition 5

Proof. We prove the three assertions separately. Throughout, \(\phi\) denotes the standard \(d\)-dimensional Gaussian density.

Part (a): conditional Bayes formula. Since \(\mathbb{R}^d\) and \(\mathbb{S}_{++}^d\) are standard Borel spaces, there exists a regular conditional law \[K(\Sigma_0,A) \mathrel{\mathop{:}}= P_{X\mid\Sigma}(A\mid \Sigma_0), \qquad A\in\mathcal{B}(\mathbb{R}^d).\] Thus \(K\) is a probability kernel from \(\mathbb{S}_{++}^d\) to \(\mathbb{R}^d\), and \[\mathbb{P}(X\in A,\Sigma\in C) = \int_C K(\Sigma_0,A)\,dP_\Sigma(\Sigma_0)\] for all \(A\in\mathcal{B}(\mathbb{R}^d)\) and \(C\in\mathcal{B}(\mathbb{S}_{++}^d)\).

Because \(V\perp\!\!\!\!\perp(X,\Sigma)\), the product kernel \[K(\Sigma_0,\cdot)\otimes P_V\] is a version of \(P_{(X,V)\mid\Sigma}(\cdot\mid\Sigma_0)\). Indeed, for \(A,B\in\mathcal{B}(\mathbb{R}^d)\) and \(C\in\mathcal{B}(\mathbb{S}_{++}^d)\), \[\begin{align} \mathbb{P}(X\in A,V\in B,\Sigma\in C) &= P_V(B)\mathbb{P}(X\in A,\Sigma\in C) \\ &= \int_C K(\Sigma_0,A)P_V(B)\,dP_\Sigma(\Sigma_0). \end{align}\] The equality on rectangles determines the product kernel. For \(\Sigma_0\in\mathbb{S}_{++}^d\), define \[P^W_{\Sigma_0}(B) \mathrel{\mathop{:}}= P_{W\mid\Sigma}(B\mid\Sigma_0) \mathrel{\mathop{:}}= K(\Sigma_0,\Sigma_0^{1/2}B), \qquad B\in\mathcal{B}(\mathbb{R}^d),\] where \[\Sigma_0^{1/2}B = \{\Sigma_0^{1/2}w:w\in B\}.\] This is well-defined because \(w\mapsto\Sigma_0^{1/2}w\) is a homeomorphism of \(\mathbb{R}^d\). It is also a probability kernel. For fixed \(B\), \[P^W_{\Sigma_0}(B) = \int_{\mathbb{R}^d} \mathbf{1}_B(\Sigma_0^{-1/2}x)\,K(\Sigma_0,dx),\] and the integrand is Borel in \((\Sigma_0,x)\).

Under the chosen conditional law given \(\Sigma=\Sigma_0\), \[W=\Sigma_0^{-1/2}X, \qquad Z=W+V, \qquad W\perp\!\!\!\!\perp V, \qquad V\sim\mathcal{N}(0,I_d).\] Hence the conditional density of \(Z\) given \(\Sigma=\Sigma_0\) is \[f_{Z\mid\Sigma}(z\mid\Sigma_0) = \int_{\mathbb{R}^d} \phi(z-w)\,dP^W_{\Sigma_0}(w).\] This density is strictly positive for every \(z\in\mathbb{R}^d\).

Now define the Gaussian density with covariance \(\Sigma_0\): \[\phi_{\Sigma_0}(u) \mathrel{\mathop{:}}= \det(\Sigma_0)^{-1/2} \phi(\Sigma_0^{-1/2}u).\] Then the conditional density of \(Y\) given \(\Sigma=\Sigma_0\) is \[f_{Y\mid\Sigma}(y\mid\Sigma_0) = \int_{\mathbb{R}^d} \phi_{\Sigma_0}(y-x)\,K(\Sigma_0,dx).\] Equivalently, with \[z_0\mathrel{\mathop{:}}=\Sigma_0^{-1/2}y,\] we have \[f_{Y\mid\Sigma}(y\mid\Sigma_0) = \det(\Sigma_0)^{-1/2} f_{Z\mid\Sigma}(z_0\mid\Sigma_0).\] Therefore \[f_{Y\mid\Sigma}(y\mid\Sigma_0)>0 \qquad \text{for all }(y,\Sigma_0)\in\mathbb{R}^d\times\mathbb{S}_{++}^d .\]

For \(A\in\mathcal{B}(\mathbb{R}^d)\), define \[\Pi_{\Sigma_0,y}(A) \mathrel{\mathop{:}}= \frac{ \displaystyle \int_A \phi_{\Sigma_0}(y-x)\,K(\Sigma_0,dx) }{ f_{Y\mid\Sigma}(y\mid\Sigma_0) }.\] Then \(\Pi_{\Sigma_0,y}\) is a probability measure. For fixed \(A\), the map \[(\Sigma_0,y,x) \mapsto \mathbf{1}_A(x)\phi_{\Sigma_0}(y-x)\] is nonnegative and Borel. Hence integration against the kernel \(K(\Sigma_0,dx)\) shows that \[(\Sigma_0,y)\mapsto\Pi_{\Sigma_0,y}(A)\] is Borel measurable. Thus \(\Pi\) is a probability kernel from \(\mathbb{S}_{++}^d\times\mathbb{R}^d\) to \(\mathbb{R}^d\).

We now verify that \(\Pi\) is a version of \(P_{X\mid Y,\Sigma}\). Let \(A,B\in\mathcal{B}(\mathbb{R}^d)\) and \(C\in\mathcal{B}(\mathbb{S}_{++}^d)\). Then \[\begin{align} &\int_C\int_B \Pi_{\Sigma_0,y}(A) f_{Y\mid\Sigma}(y\mid\Sigma_0)\,dy\,dP_\Sigma(\Sigma_0) \\ &\qquad = \int_C\int_B \int_A \phi_{\Sigma_0}(y-x)\,K(\Sigma_0,dx)\,dy\,dP_\Sigma(\Sigma_0) \\ &\qquad = \int_C \int_{\mathbb{R}^d} \int_{\mathbb{R}^d} \mathbf{1}_A(x)\mathbf{1}_B(y) \phi_{\Sigma_0}(y-x)\,dy\, K(\Sigma_0,dx)\,dP_\Sigma(\Sigma_0) \\ &\qquad = \mathbb{P}(X\in A,Y\in B,\Sigma\in C). \end{align}\] Therefore \(\Pi_{\Sigma_0,y}\) is a Bayes version of \(P_{X\mid Y,\Sigma}(\cdot\mid y,\Sigma_0)\).

In the rest of the proof, the expression \[\mathbb{E}[g(X)\mid Y=y,\Sigma=\Sigma_0]\] is understood with respect to this version. If \[\int_{\mathbb{R}^d} |g(x)|\phi_{\Sigma_0}(y-x)\,K(\Sigma_0,dx)<\infty,\] then \[\mathbb{E}[g(X)\mid Y=y,\Sigma=\Sigma_0] = \frac{ \displaystyle \int_{\mathbb{R}^d} g(x)\phi_{\Sigma_0}(y-x)\,K(\Sigma_0,dx) }{ f_{Y\mid\Sigma}(y\mid\Sigma_0) }.\] Using the definition of \(P^W_{\Sigma_0}\), the numerator becomes \[\int_{\mathbb{R}^d} g(x)\phi_{\Sigma_0}(y-x)\,K(\Sigma_0,dx) = \det(\Sigma_0)^{-1/2} \int_{\mathbb{R}^d} g(\Sigma_0^{1/2}w)\phi(z_0-w)\,dP^W_{\Sigma_0}(w).\] The same determinant factor appears in \[f_{Y\mid\Sigma}(y\mid\Sigma_0) = \det(\Sigma_0)^{-1/2} f_{Z\mid\Sigma}(z_0\mid\Sigma_0).\] After cancellation, \[\mathbb{E}[g(X)\mid Y=y,\Sigma=\Sigma_0] = \frac{ \displaystyle \int_{\mathbb{R}^d} g(\Sigma_0^{1/2}w)\phi(z_0-w)\,dP^W_{\Sigma_0}(w) }{ f_{Z\mid\Sigma}(z_0\mid\Sigma_0) }.\] This proves part (a).

Part (b): standardized Tweedie functional. Fix \(\Sigma_0\in\mathbb{S}_{++}^d\) and \(y\in\mathbb{R}^d\), and set \[z_0=\Sigma_0^{-1/2}y.\] Define \[\lambda_{g,y,\Sigma_0}(w) \mathrel{\mathop{:}}= g(\Sigma_0^{1/2}w)\phi(z_0-w).\] Assume that \[\lambda_{g,y,\Sigma_0}\in C_0(\mathbb{R}^d;\mathbb{C}).\]

For the standardized Gaussian noise, \(f_V=\phi\) and \[\varphi_V(\omega)=e^{-\|\omega\|_2^2/2}.\] The characteristic function is nowhere zero, so the convolution operator \(\mu\mapsto \phi*\mu\) is injective on \(\mathcal{M}(\mathbb{R}^d)\). Therefore, for \(f=\phi*\mu\in\mathcal{A}_V(\mathbb{R}^d)\), the measure \(\mu\) is unique.

Define \[\mathcal{T}_{g,y,\Sigma_0}[f] \mathrel{\mathop{:}}= \int_{\mathbb{R}^d} \lambda_{g,y,\Sigma_0}(w)\,d\mu(w), \qquad f=\phi*\mu.\] This is well-defined and linear. Moreover, \[\begin{align} |\mathcal{T}_{g,y,\Sigma_0}[\phi*\mu]| &\le \|\lambda_{g,y,\Sigma_0}\|_\infty \|\mu\|_{TV} \\ &= \|\lambda_{g,y,\Sigma_0}\|_\infty \|\phi*\mu\|_{\mathcal{A}_V}. \end{align}\] Thus \[\mathcal{T}_{g,y,\Sigma_0}\in\mathcal{A}_V'(\mathbb{R}^d).\] Uniqueness follows from the same injectivity argument: any continuous linear functional with this integral representation must agree with \(\mathcal{T}_{g,y,\Sigma_0}\) on every element of \(\mathcal{A}_V(\mathbb{R}^d)\).

Since \[f_{Z\mid\Sigma}(\cdot\mid\Sigma_0) = \phi*P^W_{\Sigma_0},\] we have \[\mathcal{T}_{g,y,\Sigma_0} \bigl[f_{Z\mid\Sigma}(\cdot\mid\Sigma_0)\bigr] = \int_{\mathbb{R}^d} g(\Sigma_0^{1/2}w)\phi(z_0-w)\,dP^W_{\Sigma_0}(w).\] Combining this identity with part (a) gives \[\mathbb{E}[g(X)\mid Y=y,\Sigma=\Sigma_0] = \frac{ \mathcal{T}_{g,y,\Sigma_0} \bigl[f_{Z\mid\Sigma}(\cdot\mid\Sigma_0)\bigr] }{ f_{Z\mid\Sigma}(z_0\mid\Sigma_0) }.\] This proves part (b).

Part (c): Fourier representation. Fix \(\Sigma_0\in\mathbb{S}_{++}^d\) and \(y\in\mathbb{R}^d\), and keep \[z_0=\Sigma_0^{-1/2}y.\] Consider the standardized model \[W\sim P^W_{\Sigma_0}, \qquad V\sim\mathcal{N}(0,I_d), \qquad W\perp\!\!\!\!\perp V, \qquad Z=W+V.\] In this model, the noise density is \(\phi\), the characteristic function \[\varphi_V(\omega)=e^{-\|\omega\|_2^2/2}\] is nowhere zero, and \(\phi\in C_0^k(\mathbb{R}^d)\) for every \(k\ge0\).

Assume the hypotheses in part (c). In particular, \[\lambda_{g,y,\Sigma_0}\in C_0(\mathbb{R}^d;\mathbb{C}),\] conditions (i) and (ii) of Theorem 2 hold for \(\mathcal{Q}_{g,y,\Sigma_0}\), and \(\mathcal{Q}_{g,y,\Sigma_0}\) is a Fourier-domain representer for \(\lambda_{g,y,\Sigma_0}\). Therefore Theorem 2 applies to the standardized Gaussian model.

Set \[Q_{\Sigma_0,y} \mathrel{\mathop{:}}= \mathcal{Q}_{g,y,\Sigma_0}.\] The theorem implies that \[\mathcal{F}^{-1}\{\mathcal{I}_{Q_{\Sigma_0,y}}\}\] extends continuously to \(\Xi^k(\mathbb{R}^d;\mathbb{C})\), and that its restriction to \(\mathcal{A}_V(\mathbb{R}^d)\) equals \(\mathcal{T}_{g,y,\Sigma_0}\). Hence, for every \(f\in\mathcal{A}_V(\mathbb{R}^d)\) and every sequence \((f_n)_{n\ge1}\subset\mathscr S(\mathbb{R}^d)\) such that \[\|f_n-f\|_{\Xi^k}\to0,\] we have \[\mathcal{T}_{g,y,\Sigma_0}[f] = \lim_{n\to\infty} \mathcal{F}^{-1}\{\mathcal{I}_{Q_{\Sigma_0,y}}\}[f_n].\] Equivalently, using the Fourier convention fixed above, \[\mathcal{T}_{g,y,\Sigma_0}[f] = \lim_{n\to\infty} \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} Q_{\Sigma_0,y}(\omega)\widetilde{f}_n(-\omega)\,d\omega .\] The limit is independent of the approximating sequence.

Taking \[f=f_{Z\mid\Sigma}(\cdot\mid\Sigma_0) = \phi*P^W_{\Sigma_0}\] gives \[\mathcal{T}_{g,y,\Sigma_0} \bigl[f_{Z\mid\Sigma}(\cdot\mid\Sigma_0)\bigr] = \lim_{n\to\infty} \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} Q_{\Sigma_0,y}(\omega)\widetilde{f}_n(-\omega)\,d\omega ,\] for any \((f_n)_{n\ge1}\subset\mathscr S(\mathbb{R}^d)\) satisfying \[\|f_n-f_{Z\mid\Sigma}(\cdot\mid\Sigma_0)\|_{\Xi^k}\to0.\] Combining this with the ratio from part (b) yields \[\mathbb{E}[g(X)\mid Y=y,\Sigma=\Sigma_0] = \frac{1}{f_{Z\mid\Sigma}(z_0\mid\Sigma_0)} \lim_{n\to\infty} \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} Q_{\Sigma_0,y}(\omega)\widetilde{f}_n(-\omega)\,d\omega .\] This proves part (c). ◻

1.0.1.3 Integrable Fourier representers

This section records a simple class of Tweedie functionals for which the Fourier-domain representer is integrable. In this case, the inverse Fourier transform is an ordinary bounded continuous function, and the Tweedie functional can be written as an expectation with respect to the observed density.

Proposition 6 (Expectation representation). Assume Assumptions 2 and 4 hold with smoothness order \(k=0\). Fix \(y\in\mathbb{R}^d\), and let \(g:\mathbb{R}^d\to\mathbb{R}\) be measurable. Suppose that \[\lambda_{g,V,y}\in C_0(\mathbb{R}^d;\mathbb{C}),\] and let \(Q\mathrel{\mathop{:}}=\mathcal{Q}_{g,V,y}\) be a Fourier-domain representer for \(\lambda_{g,V,y}\). If \[Q\in L^1(\mathbb{R}^d;\mathbb{C}),\] then, for every \(f\in\mathcal{A}_V(\mathbb{R}^d)\), \[\mathcal{T}_{g,V,y}[f] = \int_{\mathbb{R}^d} Q^\sharp(z)f(z)\,dz .\]

If, in addition, Assumptions 1 and 3 hold, then, whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{1}{f_Y(y)} \int_{\mathbb{R}^d} Q^\sharp(z)f_Y(z)\,dz = \frac{\mathbb{E}[Q^\sharp(Y)]}{f_Y(y)} .\]

The proposition says that an \(L^1\) Fourier-domain representer turns the Tweedie numerator into an ordinary expectation under the observed law. Thus a sample average of \(Q^\sharp(Y)\) estimates the numerator directly.

Example 4 (A Gaussian expectation representation). Suppose \(d=1\), \[Y=X+V, \qquad X\perp\!\!\!\!\perp V, \qquad V\sim\mathcal{N}(0,1).\] Fix \(a>1\), and define \[g(x) = \frac{1}{a} \exp\!\left( \frac{a^2-1}{2a^2}x^2 \right).\] For fixed \(y\in\mathbb{R}\), \[\lambda_{g,V,y}(x) = g(x)f_V(y-x).\] Since \[f_V(u) = \frac{1}{\sqrt{2\pi}}e^{-u^2/2},\] completion of the square gives \[\lambda_{g,V,y}(x) = e^{(a^2-1)y^2/2} \frac{1}{\sqrt{2\pi}\,a} \exp\!\left( -\frac{(x-a^2y)^2}{2a^2} \right).\] Therefore \[\widetilde{\lambda}_{g,V,y}(\omega) = \exp\!\left( \frac{(a^2-1)y^2}{2} +i\omega a^2y -\frac{a^2\omega^2}{2} \right).\] Since \[\varphi_V(\omega)=e^{-\omega^2/2},\] a Fourier-domain representer is \[Q(\omega) = \frac{\widetilde{\lambda}_{g,V,y}(\omega)}{\varphi_V(-\omega)} = \exp\!\left( \frac{(a^2-1)y^2}{2} +i\omega a^2y -\frac{(a^2-1)\omega^2}{2} \right).\] Because \(a>1\), we have \(Q\in L^1(\mathbb{R})\). Its inverse Fourier transform is \[Q^\sharp(z) = e^{(a^2-1)y^2/2} \frac{1}{\sqrt{2\pi(a^2-1)}} \exp\!\left( -\frac{(z-a^2y)^2}{2(a^2-1)} \right).\] Proposition 6 gives \[\mathcal{T}_{g,V,y}[f_Y] = \mathbb{E}\!\left[Q^\sharp(Y)\right].\] Consequently, whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{ \mathbb{E}\!\left[Q^\sharp(Y)\right] }{ f_Y(y) }.\]

1.0.1.3.1 Proof of Proposition 6

Proof. Write \[Q\mathrel{\mathop{:}}=\mathcal{Q}_{g,V,y}.\]

Step 1: temperedness. Since \(Q\in L^1(\mathbb{R}^d;\mathbb{C})\), the functional \[\mathcal{I}_Q[\psi] = \int_{\mathbb{R}^d}Q(\omega)\psi(\omega)\,d\omega, \qquad \psi\in\mathscr S(\mathbb{R}^d),\] is well-defined. Moreover, \[|\mathcal{I}_Q[\psi]| \le \|Q\|_1\|\psi\|_\infty .\] Thus \[\mathcal{I}_Q\in\mathscr S'(\mathbb{R}^d).\]

Step 2: inverse Fourier transform on the Schwartz class. Define \[Q^\sharp(z) \mathrel{\mathop{:}}= \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d}e^{-i\omega^\top z}Q(\omega)\,d\omega .\] By the Riemann–Lebesgue lemma, \[Q^\sharp\in C_0(\mathbb{R}^d;\mathbb{C}),\] and \[\|Q^\sharp\|_\infty \le (2\pi)^{-d}\|Q\|_1 .\]

Let \(\psi\in\mathscr S(\mathbb{R}^d)\). Since \[\int_{\mathbb{R}^d}\int_{\mathbb{R}^d} |Q(\omega)\psi(z)|\,d\omega\,dz = \|Q\|_1\|\psi\|_1 <\infty,\] Fubini’s theorem applies. Therefore \[\begin{align} \int_{\mathbb{R}^d}Q^\sharp(z)\psi(z)\,dz &= \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} Q(\omega) \left[ \int_{\mathbb{R}^d}e^{-i\omega^\top z}\psi(z)\,dz \right]d\omega \\ &= \frac{1}{(2\pi)^d} \int_{\mathbb{R}^d} Q(\omega)\widetilde{\psi}(-\omega)\,d\omega \\ &= \int_{\mathbb{R}^d} Q(\omega)\psi^\sharp(\omega)\,d\omega \\ &= \mathcal{I}_Q[\psi^\sharp] \\ &= \mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi]. \end{align}\] Hence \[\mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi] = \int_{\mathbb{R}^d}Q^\sharp(z)\psi(z)\,dz, \qquad \psi\in\mathscr S(\mathbb{R}^d).\]

Step 3: extension to \(\Xi^0\) and application of the master theorem. Define \[L[f] \mathrel{\mathop{:}}= \int_{\mathbb{R}^d}Q^\sharp(z)f(z)\,dz, \qquad f\in L^1(\mathbb{R}^d;\mathbb{C}).\] Since \(Q^\sharp\in L^\infty(\mathbb{R}^d;\mathbb{C})\), \[|L[f]| \le \|Q^\sharp\|_\infty\|f\|_1.\] In particular, for \(f\in\Xi^0(\mathbb{R}^d;\mathbb{C})\), \[|L[f]| \le \|Q^\sharp\|_\infty\|f\|_{\Xi^0}.\] Thus \(L\) is continuous on \(\Xi^0(\mathbb{R}^d;\mathbb{C})\). Step 2 shows that \(L\) extends \(\mathcal{F}^{-1}\{\mathcal{I}_Q\}\) from \(\mathscr S(\mathbb{R}^d)\) to \(\Xi^0(\mathbb{R}^d;\mathbb{C})\).

The assumptions of the proposition give the standing hypotheses of Theorem 2. Moreover, Step 1 verifies condition (i), the preceding bound verifies condition (ii) with \(k=0\), and the assumption that \(Q\) is a Fourier-domain representer for \(\lambda_{g,V,y}\) gives condition (iii). Therefore Theorem 2 gives, for every \(f\in\mathcal{A}_V(\mathbb{R}^d)\),

\[\mathcal{T}_{g,V,y}[f] = L[f] = \int_{\mathbb{R}^d}Q^\sharp(z)f(z)\,dz .\]

Now assume Assumptions 1 and 3. By Proposition 1, \[f_Y = f_V*P_X \in \mathcal{A}_V(\mathbb{R}^d).\] Taking \(f=f_Y\) in the preceding display gives \[\mathcal{T}_{g,V,y}[f_Y] = \int_{\mathbb{R}^d}Q^\sharp(z)f_Y(z)\,dz.\] Since \(Q^\sharp\) is bounded, the right-hand side equals \[\mathbb{E}[Q^\sharp(Y)].\] Finally, the ratio formula 3 yields, whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{\mathcal{T}_{g,V,y}[f_Y]}{f_Y(y)} = \frac{\mathbb{E}[Q^\sharp(Y)]}{f_Y(y)}.\] ◻

Additional supporting material

This supplement collects material that supports the main results but is not needed in the main line of the paper. The first part extends the pointwise Tweedie functional to a global operator acting on the class of mixtures for which \(g(X)\) is integrable. This gives an operator-level version of the posterior numerator and yields a smoothness statement for the posterior mean.

The second part records additional families of Fourier-domain representations. These include Hilbert-transform representers, and one-sided compensated kernels. These results are useful for identifying closed-form Tweedie functionals beyond the cases stated in the main text.

The final part gives the detailed computations behind the examples and tables. It derives the posterior mean formulas for several one-dimensional noise laws, works out functionals under the conventional Laplace mechanism, and records formulas for the heteroskedastic Gaussian sequence model. These computations are included to make the table entries and applications reproducible.

1.0.1.4 The Tweedie operator

This section passes from the pointwise identity at a fixed \(y\) to the posterior mean as an integrable \(\sigma(Y)\)-measurable random variable. The main step is to restrict attention to priors for which \(g(X)\) is integrable.

For a measurable function \(g:\mathbb{R}^d\to\mathbb{R}\), define \[\mathcal{M}_g(\mathbb{R}^d) \mathrel{\mathop{:}}= \left\{ \mu\in\mathcal{M}(\mathbb{R}^d): \int_{\mathbb{R}^d}|g(x)|\,d|\mu|(x)<\infty \right\},\] and \[\mathcal{A}_{V,g}(\mathbb{R}^d) \mathrel{\mathop{:}}= \mathcal{K}_V\bigl(\mathcal{M}_g(\mathbb{R}^d)\bigr).\] Thus \(\mathcal{A}_{V,g}(\mathbb{R}^d)\) is the class of \(V\)-mixtures whose mixing measures integrate \(|g|\). The next lemma identifies this class as the global domain on which the posterior mean exists in the usual \(L^1\) sense.

Lemma 4 (Global domain). Let \(X\sim P_X\), and let \(g:\mathbb{R}^d\to\mathbb{R}\) be measurable. Then \[\mathbb{E}[g(X)\mid Y]\] exists as an integrable \(\sigma(Y)\)-measurable random variable if and only if \[P_X\in\mathcal{M}_g(\mathbb{R}^d).\]

Proof. Set \[Z\mathrel{\mathop{:}}=g(X).\] The conditional expectation \(\mathbb{E}[Z\mid Y]\) exists as an integrable \(\sigma(Y)\)-measurable random variable if and only if \(Z\in L^1\). Since the marginal law of \(X\) is \(P_X\), \[\mathbb{E}|Z| = \int_{\mathbb{R}^d}|g(x)|\,dP_X(x).\] Thus \(Z\in L^1\) if and only if \[\int_{\mathbb{R}^d}|g(x)|\,dP_X(x)<\infty .\] Because \(P_X\) is a probability measure, \(|P_X|=P_X\), so this condition is equivalent to \[P_X\in\mathcal{M}_g(\mathbb{R}^d).\] ◻

The pointwise functionals \(\{\mathcal{T}_{g,V,y}:y\in\mathbb{R}^d\}\) can now be assembled into a single operator. Instead of fixing \(y\), the operator returns the numerator function \[y\longmapsto \int_{\mathbb{R}^d}g(x)f_V(y-x)\,d\mu(x).\] Pointwise evaluation then recovers the scalar Tweedie functional: \[(\mathscr T_{g,V}[f])(y) = \mathcal{T}_{g,V,y}[f],\] whenever the latter is defined.

Proposition 7 (The Tweedie operator). Assume Assumptions 2 and 4 hold for some \(k\ge0\). Let \(g:\mathbb{R}^d\to\mathbb{R}\) be measurable. Then there exists a unique linear operator \[\mathscr T_{g,V}: \mathcal{A}_{V,g}(\mathbb{R}^d) \to \Xi^k(\mathbb{R}^d;\mathbb{C})\] such that, for every \(\mu\in\mathcal{M}_g(\mathbb{R}^d)\), \[\mathscr T_{g,V}\bigl[\mathcal{K}_V[\mu]\bigr] = \int_{\mathbb{R}^d}g(x)\tau_x f_V\,d\mu(x) \qquad \text{in } \Xi^k(\mathbb{R}^d;\mathbb{C}),\] where the integral is understood in the Bochner sense with respect to the finite complex measure \(\mu\).

Moreover, if \(f=\mathcal{K}_V[\mu]\in\mathcal{A}_{V,g}(\mathbb{R}^d)\), then \[(\mathscr T_{g,V}[f])(y) = \int_{\mathbb{R}^d}g(x)f_V(y-x)\,d\mu(x), \qquad y\in\mathbb{R}^d.\] If, in addition, \[\lambda_{g,V,y}\in C_0(\mathbb{R}^d;\mathbb{C}),\] then \[(\mathscr T_{g,V}[f])(y) = \mathcal{T}_{g,V,y}[f].\]

Finally, suppose that \(P_X\in\mathcal{M}_g(\mathbb{R}^d)\) and that Assumptions 1 and 3 hold. Let \[f_Y = \mathcal{K}_V[P_X] \in \mathcal{A}_{V,g}(\mathbb{R}^d).\] Then \[\mathbb{E}[g(X)\mid Y] = \frac{\mathscr T_{g,V}[f_Y](Y)}{f_Y(Y)} \qquad \mathbb{P}\text{-almost surely}.\]

Proof. Let \[f=\mathcal{K}_V[\mu]\in\mathcal{A}_{V,g}(\mathbb{R}^d).\] By Assumption 2, the representing measure \(\mu\) is unique.

We first show that the Bochner integral is well-defined. By Assumption 4, \[f_V\in\Xi^k(\mathbb{R}^d;\mathbb{C}).\] By Lemma 3, the map \[x\longmapsto \tau_x f_V\] is continuous from \(\mathbb{R}^d\) into \(\Xi^k(\mathbb{R}^d;\mathbb{C})\). Since \(g\) is measurable and scalar multiplication is continuous, the map \[x\longmapsto g(x)\tau_x f_V\] is strongly measurable. Translations are isometries on \(\Xi^k\), so \[\|g(x)\tau_x f_V\|_{\Xi^k} = |g(x)|\|f_V\|_{\Xi^k}.\] Therefore \[\int_{\mathbb{R}^d} \|g(x)\tau_x f_V\|_{\Xi^k}\,d|\mu|(x) = \|f_V\|_{\Xi^k} \int_{\mathbb{R}^d}|g(x)|\,d|\mu|(x) <\infty,\] because \(\mu\in\mathcal{M}_g(\mathbb{R}^d)\). Hence \(x\mapsto g(x)\tau_x f_V\) is Bochner integrable with respect to \(\mu\).

Define \[\mathscr T_{g,V}[f] \mathrel{\mathop{:}}= \int_{\mathbb{R}^d}g(x)\tau_x f_V\,d\mu(x).\] The definition is unambiguous because \(\mu=\mathcal{K}_V^{-1}[f]\) is unique. Linearity follows from the linearity of \(\mathcal{K}_V^{-1}\) and of the Bochner integral. This proves existence and uniqueness of the operator with the displayed representation.

We now identify its pointwise values. For each \(y\in\mathbb{R}^d\), evaluation at \(y\) is a continuous linear functional on \(\Xi^k(\mathbb{R}^d;\mathbb{C})\), because \[|h(y)|\le \|h\|_\infty\le \|h\|_{\Xi^k}.\] Thus evaluation commutes with the Bochner integral: \[\begin{align} (\mathscr T_{g,V}[f])(y) &= \int_{\mathbb{R}^d} g(x)(\tau_x f_V)(y)\,d\mu(x) \\ &= \int_{\mathbb{R}^d} g(x)f_V(y-x)\,d\mu(x). \end{align}\] If \(\lambda_{g,V,y}\in C_0(\mathbb{R}^d;\mathbb{C})\), then Theorem 1 gives \[\mathcal{T}_{g,V,y}[f] = \int_{\mathbb{R}^d} g(x)f_V(y-x)\,d\mu(x).\] Hence \[(\mathscr T_{g,V}[f])(y) = \mathcal{T}_{g,V,y}[f].\]

It remains to prove the almost-sure posterior representation. Suppose that \(P_X\in\mathcal{M}_g(\mathbb{R}^d)\) and that Assumptions 1 and 3 hold. By Proposition 1, \[f_Y = f_V*P_X = \mathcal{K}_V[P_X],\] so \[f_Y\in\mathcal{A}_{V,g}(\mathbb{R}^d).\] Moreover, since \(f_V\) is bounded under Assumption 4, \[\int_{\mathbb{R}^d} |g(x)|f_V(y-x)\,dP_X(x) \le \|f_V\|_\infty \int_{\mathbb{R}^d}|g(x)|\,dP_X(x) <\infty.\] Thus the pointwise ratio formula applies for every \(y\) such that \(f_Y(y)>0\): \[\mathbb{E}[g(X)\mid Y=y] = \frac{ \displaystyle \int_{\mathbb{R}^d}g(x)f_V(y-x)\,dP_X(x) }{ f_Y(y) }.\] Using the pointwise identity above with \(\mu=P_X\), we obtain \[\mathbb{E}[g(X)\mid Y=y] = \frac{(\mathscr T_{g,V}[f_Y])(y)}{f_Y(y)}, \qquad f_Y(y)>0.\]

Finally, \[\mathbb{P}\{f_Y(Y)=0\} = P_Y\{y:f_Y(y)=0\} = \int_{\{y:f_Y(y)=0\}}f_Y(y)\,dy = 0.\] Hence the ratio is defined \(\mathbb{P}\)-almost surely, with arbitrary values on \(\{f_Y(Y)=0\}\). Therefore \[\mathbb{E}[g(X)\mid Y] = \frac{\mathscr T_{g,V}[f_Y](Y)}{f_Y(Y)} \qquad \mathbb{P}\text{-almost surely}.\] ◻

Proposition 7 factors the pointwise Tweedie functional as \[\mathcal{T}_{g,V,y} = \operatorname{ev}_y\circ \mathscr T_{g,V}.\] Thus the dependence on \(y\) enters only through evaluation after the global operator \(\mathscr T_{g,V}\) has acted on \(f_Y\). This factorization gives a direct regularity statement for the posterior mean.

Corollary 2 (Smoothness of the posterior mean). Assume the hypotheses of the final assertion of Proposition 7. Then \(\mathbb{E}[g(X)\mid Y]\) admits the version \[\theta_V^g(y) = \frac{(\mathscr T_{g,V}[f_Y])(y)}{f_Y(y)}, \qquad f_Y(y)>0.\] This version is \(k\)-times continuously differentiable on the open set \[\mathcal{O}_Y \mathrel{\mathop{:}}= \{y\in\mathbb{R}^d:f_Y(y)>0\}.\]

Proof. By Proposition 7, \[N_g \mathrel{\mathop{:}}= \mathscr T_{g,V}[f_Y] \in \Xi^k(\mathbb{R}^d;\mathbb{C}).\] By Lemma 1(b), \[f_Y=\mathcal{K}_V[P_X]\in\Xi^k(\mathbb{R}^d;\mathbb{C}).\] Hence \(N_g\) and \(f_Y\) both belong to \(C^k(\mathbb{R}^d;\mathbb{C})\).

Since \(f_Y\) is continuous, \[\mathcal{O}_Y = \{y\in\mathbb{R}^d:f_Y(y)>0\}\] is open. On \(\mathcal{O}_Y\), the denominator does not vanish. Therefore the quotient rule gives \[\frac{N_g}{f_Y} \in C^k(\mathcal{O}_Y;\mathbb{C}).\] By Proposition 7, this quotient is a version of \(\mathbb{E}[g(X)\mid Y]\) on \(\mathcal{O}_Y\). ◻

1.0.1.5 Detailed computations for the table formulas

1.0.1.5.1 Posterior means under one-dimensional noise laws

This section records the Fourier calculations underlying the entries in Table [tab:noise-families]. We specialize to the posterior mean case \(g(x)=x\) in dimension \(d=1\). Thus \[\lambda_{g,V,y}(x) = x f_V(y-x).\] The calculation has two steps. First, we find a Fourier-domain representer \(\mathcal{Q}_{g,V,y}\) using Theorem 2. Second, we identify the inverse Fourier transform \[\mathcal{F}^{-1}\{\mathcal{I}_{\mathcal{Q}_{g,V,y}}\}\] using the distributional identities developed in Section 0.0.4.

1.0.1.5.1.1 A universal one-dimensional symbol

The next lemma isolates the calculation used in the examples below. The same identity appears in [20], Equation 6.4.

Lemma 5 (Universal Fourier-domain representer for posterior means). Assume \(d=1\), let \(g(x)=x\), and fix \(y\in\mathbb{R}\). Define \[\lambda_{g,V,y}(x) \mathrel{\mathop{:}}= x f_V(y-x).\] Suppose that \[\lambda_{g,V,y}\in \Xi^0(\mathbb{R};\mathbb{C}).\] Let \[Z_V \mathrel{\mathop{:}}= \{\omega\in\mathbb{R}:\varphi_V(-\omega)=0\}.\] If \(Z_V\) has Lebesgue measure zero, then the function \[\mathcal{Q}_{g,V,y}(\omega) \mathrel{\mathop{:}}= \begin{cases} \displaystyle e^{i\omega y} \left[ y - i \frac{\frac{d}{d\omega}\varphi_V(-\omega)}{\varphi_V(-\omega)} \right], & \omega\notin Z_V, \\[2.0ex] 0, & \omega\in Z_V, \end{cases}\] is a Fourier-domain representer for \(\lambda_{g,V,y}\).

Proof. By definition, \[\widetilde{\lambda}_{g,V,y}(\omega) = \int_{\mathbb{R}} e^{i\omega x}x f_V(y-x)\,dx .\] Make the change of variables \(u=y-x\). Then \(x=y-u\), and \[\widetilde{\lambda}_{g,V,y}(\omega) = \int_{\mathbb{R}} e^{i\omega(y-u)}(y-u)f_V(u)\,du .\] Therefore \[\widetilde{\lambda}_{g,V,y}(\omega) = e^{i\omega y} \left[ y \int_{\mathbb{R}}e^{-i\omega u}f_V(u)\,du - \int_{\mathbb{R}}u e^{-i\omega u}f_V(u)\,du \right].\] The first integral is \(\varphi_V(-\omega)\).

It remains to identify the second integral. Since \(\lambda_{g,V,y}\in L^1(\mathbb{R})\), the same change of variables gives \[\int_{\mathbb{R}}|y-u|f_V(u)\,du<\infty .\] Because \(f_V\) is a probability density, \[\int_{\mathbb{R}}|u|f_V(u)\,du \le \int_{\mathbb{R}}|y-u|f_V(u)\,du + |y|\int_{\mathbb{R}}f_V(u)\,du <\infty .\] Thus \(u\mapsto u f_V(u)\) is integrable. By dominated convergence, \[\frac{d}{d\omega}\varphi_V(-\omega) = \frac{d}{d\omega} \int_{\mathbb{R}}e^{-i\omega u}f_V(u)\,du = \int_{\mathbb{R}}(-iu)e^{-i\omega u}f_V(u)\,du .\] Hence \[\int_{\mathbb{R}}u e^{-i\omega u}f_V(u)\,du = i\frac{d}{d\omega}\varphi_V(-\omega).\] Substituting this identity into the expression for \(\widetilde{\lambda}_{g,V,y}\) gives \[\widetilde{\lambda}_{g,V,y}(\omega) = e^{i\omega y} \left[ y\varphi_V(-\omega) - i\frac{d}{d\omega}\varphi_V(-\omega) \right].\]

On \(Z_V^c\), division by \(\varphi_V(-\omega)\) gives \[\frac{\widetilde{\lambda}_{g,V,y}(\omega)}{\varphi_V(-\omega)} = e^{i\omega y} \left[ y - i \frac{\frac{d}{d\omega}\varphi_V(-\omega)}{\varphi_V(-\omega)} \right].\] On \(Z_V\), we set \(\mathcal{Q}_{g,V,y}=0\). Since \(Z_V\) is Lebesgue null, \[\mathcal{Q}_{g,V,y}(\omega)\varphi_V(-\omega) = \widetilde{\lambda}_{g,V,y}(\omega) \qquad \text{for Lebesgue-a.e. }\omega .\] Thus \(\mathcal{Q}_{g,V,y}\) is a Fourier-domain representer. ◻

1.0.1.5.1.2 Hilbert-transform representers

This subsection covers Fourier-domain representers with a singular Hilbert-transform component. We use the convention \[\mathcal{H}[h](y) \mathrel{\mathop{:}}= \frac{1}{\pi} \operatorname{p.v.} \int_{\mathbb{R}} \frac{h(z)}{y-z}\,dz = \frac{1}{\pi} \lim_{\varepsilon\downarrow0} \int_{|t|>\varepsilon} \frac{h(y-t)}{t}\,dt .\] For functions in \(\Xi^1(\mathbb{R};\mathbb{C})\), the principal value below is well-defined by the estimates in the proof.

Proposition 8 (Tweedie representation via the Hilbert transform). Assume \(d=1\), Assumption 2 holds, and Assumption 4 holds with smoothness order \(1\). Fix \(y\in\mathbb{R}\), and let \(g:\mathbb{R}\to\mathbb{R}\) be measurable. Assume \[\lambda_{g,V,y}\in C_0(\mathbb{R};\mathbb{C}),\] and let \(\mathcal{Q}_{g,V,y}\) be a Fourier-domain representer for \(\lambda_{g,V,y}\).

Suppose there exist \(c_{g,V,y}\in\mathbb{C}\) and a measurable function \(k_{g,V,y}:(0,\infty)\to\mathbb{C}\) such that \[\int_0^1 t\,|k_{g,V,y}(t)|\,dt<\infty, \qquad \int_1^\infty |k_{g,V,y}(t)|\,dt<\infty,\] and \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ -i\pi c_{g,V,y}\operatorname{sgn}(\omega) + \int_0^\infty \bigl(e^{-i\omega t}-e^{i\omega t}\bigr) k_{g,V,y}(t)\,dt \right]\] for Lebesgue-a.e. \(\omega\in\mathbb{R}\). Then, for every \(f\in\mathcal{A}_V(\mathbb{R})\), \[\mathcal{T}_{g,V,y}[f] = \pi c_{g,V,y}\mathcal{H}[f](y) + \int_0^\infty \bigl(f(y-t)-f(y+t)\bigr)k_{g,V,y}(t)\,dt .\]

If, in addition, Assumptions 1 and 3 hold, then, whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{1}{f_Y(y)} \left\{ \pi c_{g,V,y}\mathcal{H}[f_Y](y) + \int_0^\infty \bigl(f_Y(y-t)-f_Y(y+t)\bigr)k_{g,V,y}(t)\,dt \right\}.\]

Proof. Write \[c\mathrel{\mathop{:}}=c_{g,V,y}, \qquad \kappa\mathrel{\mathop{:}}=k_{g,V,y}, \qquad Q\mathrel{\mathop{:}}=\mathcal{Q}_{g,V,y}.\]

Step 1: temperedness. By assumption, \(Q\) agrees Lebesgue-a.e. with \[Q_*(\omega) \mathrel{\mathop{:}}= e^{i\omega y} \left[ -i\pi c\,\operatorname{sgn}(\omega) + q_\kappa(\omega) \right],\] where \[q_\kappa(\omega) \mathrel{\mathop{:}}= \int_0^\infty \bigl(e^{-i\omega t}-e^{i\omega t}\bigr)\kappa(t)\,dt .\] The integrability assumptions on \(\kappa\) imply that \(q_\kappa\) is well-defined. Indeed, \[|e^{-i\omega t}-e^{i\omega t}| = 2|\sin(\omega t)| \le 2\min\{|\omega|t,1\}.\] Therefore \[|q_\kappa(\omega)| \le 2|\omega|\int_0^1 t|\kappa(t)|\,dt + 2\int_1^\infty |\kappa(t)|\,dt .\] Hence there is a finite constant \(C>0\) such that \[|Q_*(\omega)| \le C(1+|\omega|), \qquad \omega\in\mathbb{R} .\] Since \(Q=Q_*\) Lebesgue-a.e., the function \(Q\) may be replaced by \(Q_*\) for distributional purposes. For any integer \(N>2\), \[\int_{\mathbb{R}} \frac{|Q(\omega)|}{(1+|\omega|)^N}\,d\omega <\infty .\] Lemma 2 gives \[\mathcal{I}_Q\in\mathscr S'(\mathbb{R}).\]

Step 2: inverse Fourier transform on the Schwartz class. Let \(\psi\in\mathscr S(\mathbb{R})\), and write \[\psi^\sharp(\omega) = (2\pi)^{-1}\widetilde{\psi}(-\omega).\] Since \(\psi^\sharp\in\mathscr S(\mathbb{R})\), \[\int_{\mathbb{R}}|\psi^\sharp(\omega)|\,d\omega<\infty, \qquad \int_{\mathbb{R}}|\omega|\,|\psi^\sharp(\omega)|\,d\omega<\infty .\] Moreover, \[\begin{align} &\int_0^\infty \int_{\mathbb{R}} \left| e^{i\omega y} \bigl(e^{-i\omega t}-e^{i\omega t}\bigr) \kappa(t)\psi^\sharp(\omega) \right| \,d\omega\,dt \\ &\qquad\le 2\int_0^1 t|\kappa(t)|\,dt \int_{\mathbb{R}}|\omega|\,|\psi^\sharp(\omega)|\,d\omega + 2\int_1^\infty |\kappa(t)|\,dt \int_{\mathbb{R}}|\psi^\sharp(\omega)|\,d\omega <\infty . \end{align}\] Thus Fubini’s theorem applies to the \(q_\kappa\)-term. Fourier inversion gives \[\int_{\mathbb{R}} e^{i\omega(y-t)}\psi^\sharp(\omega)\,d\omega = \psi(y-t), \qquad \int_{\mathbb{R}} e^{i\omega(y+t)}\psi^\sharp(\omega)\,d\omega = \psi(y+t).\] Hence \[\int_{\mathbb{R}} e^{i\omega y}q_\kappa(\omega)\psi^\sharp(\omega)\,d\omega = \int_0^\infty \bigl(\psi(y-t)-\psi(y+t)\bigr)\kappa(t)\,dt .\]

It remains to handle the singular term. Under the Fourier convention used in this paper, the identity in [56], Chapter 5, Equation 5.1.12, gives \[\mathcal{F}^{-1} \left\{ \mathcal{I}_{-i\pi\operatorname{sgn}} \right\} = -\operatorname{p.v.}\!\left(\frac{1}{\,\cdot\,}\right).\] Multiplication by \(e^{i\omega y}\) shifts the inverse transform. Therefore \[\begin{align} \mathcal{F}^{-1} \left\{ \mathcal{I}_{e^{i\omega y}(-i\pi c\operatorname{sgn}(\omega))} \right\}[\psi] &= c\operatorname{p.v.} \int_{\mathbb{R}} \frac{\psi(z)}{y-z}\,dz \\ &= \pi c\,\mathcal{H}[\psi](y). \end{align}\] Combining the regular and singular parts gives, for every \(\psi\in\mathscr S(\mathbb{R})\), \[\mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi] = \pi c\,\mathcal{H}[\psi](y) + \int_0^\infty \bigl(\psi(y-t)-\psi(y+t)\bigr)\kappa(t)\,dt .\]

Step 3: \(\Xi^1\)-continuity. For \(\psi\in\Xi^1(\mathbb{R};\mathbb{C})\), define \[L[\psi] \mathrel{\mathop{:}}= \pi c\,\mathcal{H}[\psi](y) + \int_0^\infty \bigl(\psi(y-t)-\psi(y+t)\bigr)\kappa(t)\,dt .\] We show that \(L\) is well-defined and continuous on \(\Xi^1(\mathbb{R};\mathbb{C})\).

First consider the regular integral. For \(0<t\le1\), \[\psi(y-t)-\psi(y+t) = -\int_{-t}^t \psi'(y+s)\,ds,\] so \[|\psi(y-t)-\psi(y+t)| \le 2t\|\psi'\|_\infty .\] For \(t\ge1\), \[|\psi(y-t)-\psi(y+t)| \le 2\|\psi\|_\infty .\] Therefore \[\int_0^\infty |\psi(y-t)-\psi(y+t)|\,|\kappa(t)|\,dt \le 2\|\psi'\|_\infty\int_0^1 t|\kappa(t)|\,dt + 2\|\psi\|_\infty\int_1^\infty|\kappa(t)|\,dt .\]

Now consider the Hilbert-transform term. For \(\varepsilon>0\), \[\int_{|t|>\varepsilon} \frac{\psi(y-t)}{t}\,dt = \int_\varepsilon^\infty \frac{\psi(y-t)-\psi(y+t)}{t}\,dt .\] On \(0<t\le1\), \[\frac{|\psi(y-t)-\psi(y+t)|}{t} \le 2\|\psi'\|_\infty .\] On \(t\ge1\), \[\begin{align} \int_1^\infty \frac{|\psi(y-t)|}{t}\,dt &= \int_{-\infty}^{y-1} \frac{|\psi(u)|}{y-u}\,du \le \|\psi\|_1, \\ \int_1^\infty \frac{|\psi(y+t)|}{t}\,dt &= \int_{y+1}^{\infty} \frac{|\psi(u)|}{u-y}\,du \le \|\psi\|_1 . \end{align}\] Thus the principal value defining \(\mathcal{H}[\psi](y)\) exists, and \[|\mathcal{H}[\psi](y)| \le \frac{1}{\pi} \left( 2\|\psi'\|_\infty+2\|\psi\|_1 \right).\] Combining the bounds gives a finite constant \(C_{g,V,y}\) such that \[|L[\psi]| \le C_{g,V,y}\|\psi\|_{\Xi^1}, \qquad \psi\in\Xi^1(\mathbb{R};\mathbb{C}).\] Hence \[L\in\bigl(\Xi^1(\mathbb{R};\mathbb{C})\bigr)'.\] Step 2 shows that \[L[\psi] = \mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi], \qquad \psi\in\mathscr S(\mathbb{R}).\]

Step 4: passage to mixtures. The assumptions of the proposition give the standing hypotheses of Theorem 2. Moreover, Step 1 verifies condition (i), Step 3 verifies condition (ii) with smoothness order \(1\), and the assumption that \(Q\) is a Fourier-domain representer for \(\lambda_{g,V,y}\) gives condition (iii). Therefore Theorem 2 applies.

Let \(f\in\mathcal{A}_V(\mathbb{R})\), and choose \((f_n)_{n\ge1}\subset\mathscr S(\mathbb{R})\) such that \[\|f_n-f\|_{\Xi^1}\to0 .\] Then \[\mathcal{T}_{g,V,y}[f] = \lim_{n\to\infty} \mathcal{F}^{-1}\{\mathcal{I}_Q\}[f_n].\] Using Step 2 and the continuity of \(L\), \[\lim_{n\to\infty} \mathcal{F}^{-1}\{\mathcal{I}_Q\}[f_n] = \lim_{n\to\infty}L[f_n] = L[f].\] Thus \[\mathcal{T}_{g,V,y}[f] = \pi c\,\mathcal{H}[f](y) + \int_0^\infty \bigl(f(y-t)-f(y+t)\bigr)\kappa(t)\,dt .\] Restoring \(c=c_{g,V,y}\) and \(\kappa=k_{g,V,y}\) proves the functional identity.

Finally, assume Assumptions 1 and 3. By Proposition 1, \[f_Y = f_V*P_X \in \mathcal{A}_V(\mathbb{R}).\] Taking \(f=f_Y\) in the functional identity and applying the ratio formula 3 gives, whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{1}{f_Y(y)} \left\{ \pi c_{g,V,y}\mathcal{H}[f_Y](y) + \int_0^\infty \bigl(f_Y(y-t)-f_Y(y+t)\bigr)k_{g,V,y}(t)\,dt \right\}.\] ◻

1.0.1.5.1.3 One-sided compensated kernels

The next family covers Fourier-domain representers whose inverse transform is a one-sided compensated kernel.

Proposition 9 (Tweedie representation via one-sided compensated kernels). Assume \(d=1\), Assumption 2 holds, and Assumption 4 holds with smoothness order \(1\). Fix \(y\in\mathbb{R}\), and let \(g:\mathbb{R}\to\mathbb{R}\) be measurable. Assume \[\lambda_{g,V,y}\in C_0(\mathbb{R};\mathbb{C}),\] and let \(\mathcal{Q}_{g,V,y}\) be a Fourier-domain representer for \(\lambda_{g,V,y}\).

Suppose there exist \(c_{g,V,y}\in\mathbb{C}\) and a measurable function \(k_{g,V,y}:(0,\infty)\to\mathbb{C}\) such that \[\int_0^1 t\,|k_{g,V,y}(t)|\,dt<\infty, \qquad \int_1^\infty |k_{g,V,y}(t)|\,dt<\infty,\] and \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ c_{g,V,y} + \int_0^\infty \bigl(1-e^{-i\omega t}\bigr)k_{g,V,y}(t)\,dt \right]\] for Lebesgue-a.e. \(\omega\in\mathbb{R}\). Then, for every \(f\in\mathcal{A}_V(\mathbb{R})\), \[\mathcal{T}_{g,V,y}[f] = c_{g,V,y}f(y) + \int_0^\infty \bigl(f(y)-f(y-t)\bigr)k_{g,V,y}(t)\,dt .\]

If, in addition, Assumptions 1 and 3 hold, then, whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{1}{f_Y(y)} \left\{ c_{g,V,y}f_Y(y) + \int_0^\infty \bigl(f_Y(y)-f_Y(y-t)\bigr)k_{g,V,y}(t)\,dt \right\}.\]

Proof. Write \[c\mathrel{\mathop{:}}=c_{g,V,y}, \qquad \kappa\mathrel{\mathop{:}}=k_{g,V,y}, \qquad Q\mathrel{\mathop{:}}=\mathcal{Q}_{g,V,y}.\]

Step 1: temperedness. By assumption, \(Q\) agrees Lebesgue-a.e. with \[Q_*(\omega) \mathrel{\mathop{:}}= e^{i\omega y} \bigl(c+q_\kappa(\omega)\bigr),\] where \[q_\kappa(\omega) \mathrel{\mathop{:}}= \int_0^\infty \bigl(1-e^{-i\omega t}\bigr)\kappa(t)\,dt .\] The integrability assumptions on \(\kappa\) imply that \(q_\kappa\) is well-defined. Indeed, \[|1-e^{-i\omega t}| \le \min\{2,|\omega|t\}.\] Therefore \[|q_\kappa(\omega)| \le |\omega|\int_0^1 t|\kappa(t)|\,dt + 2\int_1^\infty |\kappa(t)|\,dt .\] Hence there is a finite constant \(C>0\) such that \[|Q_*(\omega)| \le C(1+|\omega|), \qquad \omega\in\mathbb{R} .\] Since \(Q=Q_*\) Lebesgue-a.e., the two functions induce the same distribution on \(\mathscr S(\mathbb{R})\). For any integer \(N>2\), \[\int_{\mathbb{R}} \frac{|Q(\omega)|}{(1+|\omega|)^N}\,d\omega <\infty,\] after replacing \(Q\) by \(Q_*\) on a null set. Lemma 2 gives \[\mathcal{I}_Q\in\mathscr S'(\mathbb{R}).\]

Step 2: inverse Fourier transform on the Schwartz class. Let \(\psi\in\mathscr S(\mathbb{R})\), and write \[\psi^\sharp(\omega) = (2\pi)^{-1}\widetilde{\psi}(-\omega).\] Since \(\psi^\sharp\in\mathscr S(\mathbb{R})\), \[\int_{\mathbb{R}} (1+|\omega|)|\psi^\sharp(\omega)|\,d\omega <\infty .\] Moreover, \[\begin{align} &\int_0^\infty \int_{\mathbb{R}} \left| e^{i\omega y} \bigl(1-e^{-i\omega t}\bigr) \kappa(t)\psi^\sharp(\omega) \right| \,d\omega\,dt \\ &\qquad\le \int_0^1 t|\kappa(t)|\,dt \int_{\mathbb{R}}|\omega|\,|\psi^\sharp(\omega)|\,d\omega + 2\int_1^\infty |\kappa(t)|\,dt \int_{\mathbb{R}}|\psi^\sharp(\omega)|\,d\omega <\infty . \end{align}\] Thus Fubini’s theorem applies. Using \(Q=Q_*\) a.e., \[\begin{align} \mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi] &= \mathcal{I}_Q[\psi^\sharp] \\ &= \int_{\mathbb{R}}Q(\omega)\psi^\sharp(\omega)\,d\omega \\ &= c \int_{\mathbb{R}}e^{i\omega y}\psi^\sharp(\omega)\,d\omega \\ &\qquad + \int_0^\infty \left[ \int_{\mathbb{R}} e^{i\omega y} \bigl(1-e^{-i\omega t}\bigr) \psi^\sharp(\omega)\,d\omega \right]\kappa(t)\,dt . \end{align}\] Fourier inversion on \(\mathscr S(\mathbb{R})\) gives \[\int_{\mathbb{R}}e^{i\omega y}\psi^\sharp(\omega)\,d\omega = \psi(y), \qquad \int_{\mathbb{R}}e^{i\omega(y-t)}\psi^\sharp(\omega)\,d\omega = \psi(y-t).\] Therefore \[\mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi] = c\psi(y) + \int_0^\infty \bigl(\psi(y)-\psi(y-t)\bigr)\kappa(t)\,dt .\]

Step 3: \(\Xi^1\)-continuity. For \(\psi\in\Xi^1(\mathbb{R};\mathbb{C})\), define \[L[\psi] \mathrel{\mathop{:}}= c\psi(y) + \int_0^\infty \bigl(\psi(y)-\psi(y-t)\bigr)\kappa(t)\,dt .\] This is well-defined. For \(0<t\le1\), \[|\psi(y)-\psi(y-t)| \le t\|\psi'\|_\infty,\] while for \(t\ge1\), \[|\psi(y)-\psi(y-t)| \le 2\|\psi\|_\infty .\] Hence \[\begin{align} |L[\psi]| &\le |c|\,\|\psi\|_\infty + \|\psi'\|_\infty\int_0^1 t|\kappa(t)|\,dt + 2\|\psi\|_\infty\int_1^\infty |\kappa(t)|\,dt \\ &\le C_{g,V,y}\|\psi\|_{\Xi^1} \end{align}\] for some finite constant \(C_{g,V,y}\). Thus \[L\in \bigl(\Xi^1(\mathbb{R};\mathbb{C})\bigr)'.\] Step 2 shows that \[L[\psi] = \mathcal{F}^{-1}\{\mathcal{I}_Q\}[\psi], \qquad \psi\in\mathscr S(\mathbb{R}).\] Therefore condition (ii) of Theorem 2 holds with smoothness order \(1\).

Step 4: passage to mixtures. The assumptions of the proposition give the standing hypotheses of Theorem 2. Moreover, Step 1 verifies condition (i), Step 3 verifies condition (ii) with smoothness order \(1\), and the assumption that \(Q\) is a Fourier-domain representer for \(\lambda_{g,V,y}\) gives condition (iii). Therefore Theorem 2 applies.

Let \(f\in\mathcal{A}_V(\mathbb{R})\), and choose \((f_n)_{n\ge1}\subset\mathscr S(\mathbb{R})\) such that \[\|f_n-f\|_{\Xi^1}\to0 .\] Then \[\mathcal{T}_{g,V,y}[f] = \lim_{n\to\infty} \mathcal{F}^{-1}\{\mathcal{I}_Q\}[f_n].\] Using Step 2 and the continuity of \(L\), \[\lim_{n\to\infty} \mathcal{F}^{-1}\{\mathcal{I}_Q\}[f_n] = \lim_{n\to\infty}L[f_n] = L[f].\] Therefore \[\mathcal{T}_{g,V,y}[f] = c f(y) + \int_0^\infty \bigl(f(y)-f(y-t)\bigr)\kappa(t)\,dt .\] Restoring \(c=c_{g,V,y}\) and \(\kappa=k_{g,V,y}\) proves the functional identity.

Finally, assume Assumptions 1 and 3. By Proposition 1, \[f_Y = f_V*P_X \in \mathcal{A}_V(\mathbb{R}).\] Taking \(f=f_Y\) in the functional identity and applying the ratio formula 3 gives, whenever \(f_Y(y)>0\), \[\mathbb{E}[g(X)\mid Y=y] = \frac{1}{f_Y(y)} \left\{ c_{g,V,y}f_Y(y) + \int_0^\infty \bigl(f_Y(y)-f_Y(y-t)\bigr)k_{g,V,y}(t)\,dt \right\}.\] ◻

1.0.1.5.2 Computation of Table [tab:noise-families] entries

This subsection derives the formulas reported in Table [tab:noise-families]. Throughout, we work in dimension \(d=1\) and take \[g(x)=x, \qquad \lambda_{g,V,y}(x)=x f_V(y-x).\] All posterior-mean formulas below are stated for points \(y\) such that \(f_Y(y)>0\).

The calculations use Lemma 5. After computing the Fourier-domain representer \(\mathcal{Q}_{g,V,y}\), we identify its real-space action using one of the representation results from the preceding sections.

Example 5 (Normal noise). Let \[V\sim \mathrm{Normal}(\mu,\sigma^2).\] Then \[\varphi_V(-\omega) = e^{-i\mu\omega-\sigma^2\omega^2/2}.\] Lemma 5 gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y-\mu+i\sigma^2\omega \right].\] Equivalently, \[\mathcal{Q}_{g,V,y}(\omega) = (y-\mu)\varphi_{\delta_y}(\omega) + (i\omega)\varphi_{\sigma^2\delta_y}(\omega).\] Thus Proposition 4 applies with smoothness order \(k=1\), \[\mu_0=(y-\mu)\delta_y, \qquad \mu_1=\sigma^2\delta_y.\] Hence \[\mathcal{T}_{g,V,y}[f_Y] = (y-\mu)f_Y(y)+\sigma^2 f_Y'(y).\] Therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y-\mu+\sigma^2\frac{f_Y'(y)}{f_Y(y)}. }\]

Example 6 (Generalized Laplace noise). Let \[V\sim \mathrm{Generalized\;Laplace}(\mu,b,\lambda), \qquad \lambda>\frac{1}{2}.\] The condition \(\lambda>1/2\) ensures \(f_V\in C_0(\mathbb{R})\). The characteristic function satisfies \[\varphi_V(-\omega) = e^{-i\mu\omega}(1+b^2\omega^2)^{-\lambda}.\] Lemma 5 gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y-\mu+ \frac{2i\lambda b^2\omega}{1+b^2\omega^2} \right].\]

Let \(\nu_y\) be the finite signed measure with density \[d\nu_y(z) = \operatorname{sgn}(z-y)e^{-|z-y|/b}\,dz.\] A direct computation gives \[\varphi_{\nu_y}(\omega) = \frac{2ib^2\omega}{1+b^2\omega^2}e^{i\omega y}.\] Therefore \[\mathcal{Q}_{g,V,y}(\omega) = (y-\mu)\varphi_{\delta_y}(\omega) + \lambda\varphi_{\nu_y}(\omega).\] Proposition 4 applies with smoothness order \(k=0\) and \[\mu_0=(y-\mu)\delta_y+\lambda\nu_y.\] Thus \[\mathcal{T}_{g,V,y}[f_Y] = (y-\mu)f_Y(y) + \lambda \int_{\mathbb{R}} \operatorname{sgn}(z-y)e^{-|z-y|/b}f_Y(z)\,dz.\] Therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y-\mu+ \frac{\lambda}{f_Y(y)} \int_{\mathbb{R}} \operatorname{sgn}(z-y)e^{-|z-y|/b}f_Y(z)\,dz. }\]

Example 7 (Laplace noise). Let \[V\sim \mathrm{Laplace}(\mu,b).\] This is the case \(\lambda=1\) of Example 6. Hence \[\mathcal{T}_{g,V,y}[f_Y] = (y-\mu)f_Y(y) + \int_{\mathbb{R}} \operatorname{sgn}(z-y)e^{-|z-y|/b}f_Y(z)\,dz,\] and therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y-\mu+ \frac{1}{f_Y(y)} \int_{\mathbb{R}} \operatorname{sgn}(z-y)e^{-|z-y|/b}f_Y(z)\,dz. }\]

Example 8 (Asymmetric Laplace noise). Let \[V\sim \mathrm{Asymmetric\;Laplace}(\mu,b_-,b_+).\] Then \[\varphi_V(-\omega) = \frac{e^{-i\mu\omega}}{(1-i b_-\omega)(1+i b_+\omega)}.\] Lemma 5 gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y-\mu+ \frac{b_-}{1-i b_-\omega} - \frac{b_+}{1+i b_+\omega} \right].\]

Let \(\nu_y\) be the finite signed measure with density \[d\nu_y(z) = e^{-(z-y)/b_-}\mathbf{1}_{\{z\ge y\}}\,dz - e^{(z-y)/b_+}\mathbf{1}_{\{z<y\}}\,dz.\] Then \[\varphi_{\nu_y}(\omega) = e^{i\omega y} \left[ \frac{b_-}{1-i b_-\omega} - \frac{b_+}{1+i b_+\omega} \right].\] Hence \[\mathcal{Q}_{g,V,y}(\omega) = (y-\mu)\varphi_{\delta_y}(\omega) + \varphi_{\nu_y}(\omega).\] Proposition 4 applies with smoothness order \(k=0\) and \[\mu_0=(y-\mu)\delta_y+\nu_y.\] Thus \[\mathcal{T}_{g,V,y}[f_Y] = (y-\mu)f_Y(y) + \int_y^\infty e^{-(z-y)/b_-}f_Y(z)\,dz - \int_{-\infty}^y e^{(z-y)/b_+}f_Y(z)\,dz.\] Therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y-\mu+ \frac{1}{f_Y(y)} \left[ \int_y^\infty e^{-(z-y)/b_-}f_Y(z)\,dz - \int_{-\infty}^y e^{(z-y)/b_+}f_Y(z)\,dz \right]. }\]

Example 9 (Logistic noise). Let \[V\sim \mathrm{Logistic}(\mu,s).\] Then \[\varphi_V(-\omega) = e^{-i\mu\omega}\frac{\pi s\omega}{\sinh(\pi s\omega)}.\] Lemma 5 gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y-\mu + i\left\{ \pi s\,\coth(\pi s\omega)-\frac{1}{\omega} \right\} \right].\]

Using [75], Formula 3.912.2, \[\pi s\,\coth(\pi s\omega)-\frac{1}{\omega} = 2\int_0^\infty \frac{\sin(\omega t)}{e^{t/s}-1}\,dt.\] Therefore \[i\left\{ \pi s\,\coth(\pi s\omega)-\frac{1}{\omega} \right\} = - \int_0^\infty \bigl(e^{-i\omega t}-e^{i\omega t}\bigr) \frac{dt}{e^{t/s}-1}.\] Hence \[\mathcal{Q}_{g,V,y}(\omega) = (y-\mu)\varphi_{\delta_y}(\omega) - e^{i\omega y} \int_0^\infty \bigl(e^{-i\omega t}-e^{i\omega t}\bigr) \frac{dt}{e^{t/s}-1}.\]

The first term is handled by Proposition 4. The second term is handled by Proposition 8 with \[c_{g,V,y}=0, \qquad k_{g,V,y}(t) = -\frac{1}{e^{t/s}-1}.\] Thus \[\mathcal{T}_{g,V,y}[f_Y] = (y-\mu)f_Y(y) - \int_0^\infty \frac{f_Y(y-t)-f_Y(y+t)}{e^{t/s}-1}\,dt.\] Equivalently, \[\boxed{ \mathbb{E}[X\mid Y=y] = y-\mu+ \frac{1}{f_Y(y)} \int_0^\infty \frac{f_Y(y+t)-f_Y(y-t)}{e^{t/s}-1}\,dt. }\]

Example 10 (Gumbel noise). Let \[V\sim \mathrm{Gumbel}(\mu,\beta).\] Then \[\varphi_V(-\omega) = e^{-i\mu\omega}\Gamma(1+i\beta\omega).\] Lemma 5 gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y-\mu+\beta\psi_{\mathrm{DG}}(1+i\beta\omega) \right],\] where \[\psi_{\mathrm{DG}}=\frac{\Gamma'}{\Gamma}\] is the digamma function. Let \(\gamma_E\) denote the Euler–Mascheroni constant. Using [76], Formula 6.3.22, \[\psi_{\mathrm{DG}}(1+z) = -\gamma_E + \int_0^\infty \frac{1-e^{-zt}}{e^t-1}\,dt, \qquad \Re(z)>-1.\] With \(z=i\beta\omega\), and after the change of variables \(u=\beta t\), \[\beta\psi_{\mathrm{DG}}(1+i\beta\omega) = -\beta\gamma_E + \int_0^\infty \frac{1-e^{-i\omega u}}{e^{u/\beta}-1}\,du.\] Therefore \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y-\mu-\beta\gamma_E + \int_0^\infty \bigl(1-e^{-i\omega u}\bigr) \frac{du}{e^{u/\beta}-1} \right].\]

Proposition 9 applies with \[c_{g,V,y}=y-\mu-\beta\gamma_E, \qquad k_{g,V,y}(u)=\frac{1}{e^{u/\beta}-1}.\] It follows that \[\mathcal{T}_{g,V,y}[f_Y] = (y-\mu-\beta\gamma_E)f_Y(y) + \int_0^\infty \frac{f_Y(y)-f_Y(y-u)}{e^{u/\beta}-1}\,du.\] Therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y-\mu-\beta\gamma_E + \frac{1}{f_Y(y)} \int_0^\infty \frac{f_Y(y)-f_Y(y-u)}{e^{u/\beta}-1}\,du. }\]

Example 11 (Cauchy noise). Let \[V\sim \mathrm{Cauchy}(\mu,\gamma), \qquad \gamma>0.\] We again take \(g(x)=x\). In this case the universal symbol lemma does not apply. Indeed, \[\lambda_{g,V,y}(x) = x f_V(y-x) = \frac{\gamma x}{\pi\{(y-\mu-x)^2+\gamma^2\}}\] belongs to \(C_0(\mathbb{R};\mathbb{C})\), but \[x f_V(y-x) \sim \frac{\gamma}{\pi x} \qquad (|x|\to\infty).\] Thus \[\lambda_{g,V,y}\notin L^1(\mathbb{R}), \qquad \lambda_{g,V,y}\notin \Xi^0(\mathbb{R};\mathbb{C}),\] so Lemma 5 cannot be invoked.

We verify the Fourier-domain representer identity directly. Set \[a\mathrel{\mathop{:}}=y-\mu, \qquad h_y(x)\mathrel{\mathop{:}}=f_V(y-x).\] Then \(h_y\in L^1(\mathbb{R})\), and \[\widetilde{h}_y(\omega) = e^{i\omega y}\varphi_V(-\omega) = e^{i\omega(y-\mu)-\gamma|\omega|} = e^{ia\omega-\gamma|\omega|}.\] Although \(\lambda_{g,V,y}(x)=x h_y(x)\) is not integrable, it is bounded and belongs to \(C_0(\mathbb{R};\mathbb{C})\). Hence it defines a tempered distribution by integration against Schwartz functions.

Let \(\psi\in\mathscr S(\mathbb{R})\). Using the distributional identity \[\mathcal{F}\{x h_y\} = -i\frac{d}{d\omega}\widetilde{h}_y,\] we obtain \[\mathcal{F}\{\mathcal{I}_{\lambda_{g,V,y}}\}[\psi] = i\int_{\mathbb{R}} e^{ia\omega-\gamma|\omega|} \psi'(\omega)\,d\omega .\] The function \(\omega\mapsto e^{ia\omega-\gamma|\omega|}\) is absolutely continuous on \((-\infty,0)\) and \((0,\infty)\), and is continuous at \(0\). Thus integration by parts gives no boundary term at the origin, and \[\begin{align} i\int_{\mathbb{R}} e^{ia\omega-\gamma|\omega|} \psi'(\omega)\,d\omega &= -i\int_{\mathbb{R}} \frac{d}{d\omega} \left(e^{ia\omega-\gamma|\omega|}\right) \psi(\omega)\,d\omega \\ &= \int_{\mathbb{R}} e^{ia\omega-\gamma|\omega|} \left(a+i\gamma\operatorname{sgn}(\omega)\right) \psi(\omega)\,d\omega . \end{align}\] Therefore \[\mathcal{F}\{\mathcal{I}_{\lambda_{g,V,y}}\} = \mathcal{I}_{\omega\mapsto e^{ia\omega-\gamma|\omega|} \left(a+i\gamma\operatorname{sgn}(\omega)\right)} \qquad \text{in } \mathscr S'(\mathbb{R}).\]

Since \[\varphi_V(-\omega) = e^{-i\mu\omega-\gamma|\omega|},\] the function \[\mathcal{Q}_{g,V,y}(\omega) \mathrel{\mathop{:}}= e^{i\omega y} \left[ y-\mu+i\gamma\operatorname{sgn}(\omega) \right]\] satisfies \[\mathcal{Q}_{g,V,y}(\omega)\varphi_V(-\omega) = e^{ia\omega-\gamma|\omega|} \left(a+i\gamma\operatorname{sgn}(\omega)\right)\] for Lebesgue-a.e. \(\omega\). Hence \(\mathcal{Q}_{g,V,y}\) is a Fourier-domain representer for \(\lambda_{g,V,y}\).

We now decompose the representer as \[\mathcal{Q}_{g,V,y}(\omega) = (y-\mu)\varphi_{\delta_y}(\omega) - i\pi\left(-\frac{\gamma}{\pi}\right) e^{i\omega y}\operatorname{sgn}(\omega).\] The first term is a measure-factorization term with \[\mu_0=(y-\mu)\delta_y.\] The second term is the Hilbert-transform term in Proposition 8, with \[c_{g,V,y}=-\frac{\gamma}{\pi}, \qquad k_{g,V,y}\equiv0.\] Combining Proposition 4 with Proposition 8 gives \[\mathcal{T}_{g,V,y}[f_Y] = (y-\mu)f_Y(y) - \gamma\,\mathcal{H}[f_Y](y).\] Therefore, whenever \(f_Y(y)>0\), \[\boxed{ \mathbb{E}[X\mid Y=y] = y-\mu - \gamma\frac{\mathcal{H}[f_Y](y)}{f_Y(y)}. }\]

Example 12 (Hyperbolic secant noise). Let \[V\sim \mathrm{Hyperbolic\;Secant}(\mu,s), \qquad s>0.\] Then \[\varphi_V(-\omega) = e^{-i\mu\omega}\operatorname{sech}(s\omega).\] Lemma 5 gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y-\mu+i s\,\tanh(s\omega) \right].\]

Using [75], Formula 3.981.1, \[\tanh(s\omega) = \frac{1}{s} \int_0^\infty \frac{\sin(\omega t)}{\sinh\!\left(\frac{\pi t}{2s}\right)}\,dt.\] Hence \[is\,\tanh(s\omega) = - \int_0^\infty \frac{e^{-i\omega t}-e^{i\omega t}}{2\sinh\!\left(\frac{\pi t}{2s}\right)}\,dt.\] Therefore \[\mathcal{Q}_{g,V,y}(\omega) = (y-\mu)\varphi_{\delta_y}(\omega) - e^{i\omega y} \int_0^\infty \frac{e^{-i\omega t}-e^{i\omega t}}{2\sinh\!\left(\frac{\pi t}{2s}\right)}\,dt.\]

The first term is handled by Proposition 4. The second term is handled by Proposition 8 with \[c_{g,V,y}=0, \qquad k_{g,V,y}(t) = -\frac{1}{2\sinh\!\left(\frac{\pi t}{2s}\right)}.\] Thus \[\mathcal{T}_{g,V,y}[f_Y] = (y-\mu)f_Y(y) - \int_0^\infty \frac{f_Y(y-t)-f_Y(y+t)}{2\sinh\!\left(\frac{\pi t}{2s}\right)}\,dt.\] Therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y-\mu + \frac{1}{f_Y(y)} \int_0^\infty \frac{f_Y(y+t)-f_Y(y-t)}{2\sinh\!\left(\frac{\pi t}{2s}\right)}\,dt . }\]

Example 13 (Gamma noise). Let \[V\sim \mathrm{Gamma}(\alpha,\theta), \qquad \alpha>1,\quad \theta>0,\] and extend its density by zero off \((0,\infty)\). The condition \(\alpha>1\) ensures that the extended density belongs to \(C_0(\mathbb{R})\). Since \[\varphi_V(-\omega) = (1+i\theta\omega)^{-\alpha},\] Lemma 5 gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y-\frac{\alpha\theta}{1+i\theta\omega} \right].\]

Let \(\nu_y\) be the finite measure with density \[d\nu_y(z) = \frac{1}{\theta} e^{(z-y)/\theta} \mathbf{1}_{\{z<y\}}\,dz.\] A direct computation gives \[\varphi_{\nu_y}(\omega) = \frac{e^{i\omega y}}{1+i\theta\omega}.\] Therefore \[\mathcal{Q}_{g,V,y}(\omega) = y\,\varphi_{\delta_y}(\omega) - \alpha\theta\,\varphi_{\nu_y}(\omega).\] Proposition 4 applies with smoothness order \(k=0\) and \[\mu_0 = y\delta_y-\alpha\theta\nu_y.\] Hence \[\mathcal{T}_{g,V,y}[f_Y] = y f_Y(y) - \alpha \int_{-\infty}^y e^{(z-y)/\theta}f_Y(z)\,dz.\] Therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y - \frac{\alpha}{f_Y(y)} \int_{-\infty}^y e^{(z-y)/\theta}f_Y(z)\,dz . }\]

Example 14 (Noncentral chi-square noise). Let \[V\sim \mathrm{Noncentral}\;\chi^2_\nu(\delta), \qquad \nu>2,\quad \delta\ge0,\] and extend its density by zero off \((0,\infty)\). The condition \(\nu>2\) ensures that the extended density belongs to \(C_0(\mathbb{R})\). Since \[\varphi_V(-\omega) = (1+2i\omega)^{-\nu/2} \exp\!\left( -\frac{i\delta\omega}{1+2i\omega} \right),\] we have \[\frac{\frac{d}{d\omega}\varphi_V(-\omega)}{\varphi_V(-\omega)} = -\frac{i\nu}{1+2i\omega} - \frac{i\delta}{(1+2i\omega)^2}.\] Lemma 5 therefore gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y - \frac{\nu}{1+2i\omega} - \frac{\delta}{(1+2i\omega)^2} \right].\]

Let \(\eta_{1,y}\) and \(\eta_{2,y}\) be the finite measures with densities \[d\eta_{1,y}(z) = \frac{1}{2} e^{(z-y)/2}\mathbf{1}_{\{z<y\}}\,dz,\] and \[d\eta_{2,y}(z) = \frac{y-z}{4}e^{(z-y)/2}\mathbf{1}_{\{z<y\}}\,dz.\] A direct computation gives \[\varphi_{\eta_{1,y}}(\omega) = \frac{e^{i\omega y}}{1+2i\omega}, \qquad \varphi_{\eta_{2,y}}(\omega) = \frac{e^{i\omega y}}{(1+2i\omega)^2}.\] Hence \[\mathcal{Q}_{g,V,y}(\omega) = y\,\varphi_{\delta_y}(\omega) - \nu\,\varphi_{\eta_{1,y}}(\omega) - \delta\,\varphi_{\eta_{2,y}}(\omega).\] Proposition 4 applies with smoothness order \(k=0\) and \[\mu_0 = y\delta_y-\nu\eta_{1,y}-\delta\eta_{2,y}.\] Thus \[\mathcal{T}_{g,V,y}[f_Y] = y f_Y(y) - \frac{\nu}{2} \int_{-\infty}^y e^{(z-y)/2}f_Y(z)\,dz - \frac{\delta}{4} \int_{-\infty}^y (y-z)e^{(z-y)/2}f_Y(z)\,dz.\] Therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y - \frac{1}{f_Y(y)} \left[ \frac{\nu}{2} \int_{-\infty}^y e^{(z-y)/2}f_Y(z)\,dz + \frac{\delta}{4} \int_{-\infty}^y (y-z)e^{(z-y)/2}f_Y(z)\,dz \right]. }\]

Example 15 (Inverse Gaussian noise). Let \[V\sim \mathrm{Inverse\;Gaussian}(\mu,\lambda), \qquad \mu>0,\quad \lambda>0.\] Then \[\varphi_V(-\omega) = \exp\!\left[ \frac{\lambda}{\mu} \left( 1-\sqrt{1+\frac{2i\mu^2\omega}{\lambda}} \right) \right].\] Moreover, \[\frac{\frac{d}{d\omega}\varphi_V(-\omega)}{\varphi_V(-\omega)} = -\frac{i\mu}{\sqrt{1+\frac{2i\mu^2\omega}{\lambda}}}.\] Lemma 5 gives \[\mathcal{Q}_{g,V,y}(\omega) = e^{i\omega y} \left[ y - \frac{\mu}{\sqrt{1+\frac{2i\mu^2\omega}{\lambda}}} \right].\]

Let \(\nu_y\) be the finite measure with density \[d\nu_y(z) = \sqrt{\frac{\lambda}{2\pi\mu^2}}\, (y-z)^{-1/2} \exp\!\left( -\frac{\lambda(y-z)}{2\mu^2} \right) \mathbf{1}_{\{z<y\}}\,dz.\] A direct computation gives \[\varphi_{\nu_y}(\omega) = \frac{e^{i\omega y}}{\sqrt{1+\frac{2i\mu^2\omega}{\lambda}}}.\] Therefore \[\mathcal{Q}_{g,V,y}(\omega) = y\,\varphi_{\delta_y}(\omega) - \mu\,\varphi_{\nu_y}(\omega).\] Proposition 4 applies with smoothness order \(k=0\) and \[\mu_0 = y\delta_y-\mu\nu_y.\] Hence \[\mathcal{T}_{g,V,y}[f_Y] = y f_Y(y) - \sqrt{\frac{\lambda}{2\pi}} \int_{-\infty}^y (y-z)^{-1/2} \exp\!\left( -\frac{\lambda(y-z)}{2\mu^2} \right) f_Y(z)\,dz.\] Therefore \[\boxed{ \mathbb{E}[X\mid Y=y] = y - \frac{1}{f_Y(y)} \sqrt{\frac{\lambda}{2\pi}} \int_{-\infty}^y (y-z)^{-1/2} \exp\!\left( -\frac{\lambda(y-z)}{2\mu^2} \right) f_Y(z)\,dz . }\]

1.0.1.5.3 Functionals under the conventional Laplace mechanism

This section records the formulas used for the conventional Laplace mechanism from Section 0.0.5.3. The noise density is the product Laplace density \[f_V(v) = \prod_{j=1}^d \frac{1}{2b}\exp\!\left(-\frac{|v_j|}{b}\right) = \frac{1}{(2b)^d} \exp\!\left(-\frac{\|v\|_1}{b}\right), \qquad v\in\mathbb{R}^d.\] Its characteristic function is \[\varphi_V(\omega) = \prod_{j=1}^d \frac{1}{1+b^2\omega_j^2}.\]

We first define the kernels that appear in the formulas. For a measurable function \(f:\mathbb{R}^d\to\mathbb{C}\), set \[(\mathsf D_{b,j}f)(y) \mathrel{\mathop{:}}= \int_{\mathbb{R}} \operatorname{sgn}(u)e^{-|u|/b} f(y+u e_j)\,du, \qquad j=1,\ldots,d.\] Let \[(\mathsf D_b f)(y) \mathrel{\mathop{:}}= \bigl( (\mathsf D_{b,1}f)(y),\ldots, (\mathsf D_{b,d}f)(y) \bigr)^\top .\] Next define the matrix-valued operator \(\mathsf G_b\) entrywise by \[(\mathsf G_{b,jj}f)(y) \mathrel{\mathop{:}}= \int_{\mathbb{R}} (2|u|-b)e^{-|u|/b} f(y+u e_j)\,du,\] and, for \(j\neq k\), \[(\mathsf G_{b,jk}f)(y) \mathrel{\mathop{:}}= \int_{\mathbb{R}}\int_{\mathbb{R}} \operatorname{sgn}(u)\operatorname{sgn}(v) e^{-(|u|+|v|)/b} f(y+u e_j+v e_k)\,du\,dv .\] Thus \[(\mathsf G_b f)(y) = \bigl[ (\mathsf G_{b,jk}f)(y) \bigr]_{j,k=1}^d .\]

1.0.1.5.3.1 Loss functionals in the multi-dimensional Laplace mechanism

Example 16 (Posterior mean under product Laplace noise). Let \[g(x)=x.\] For the product Laplace law, the Fourier-domain representer factorizes coordinatewise. For the \(j\)-th coordinate, \[\mathcal{Q}_{j,V,y}(\omega) = e^{i\omega^\top y} \left[ y_j+ \frac{2ib^2\omega_j}{1+b^2\omega_j^2} \right].\] Let \(\nu_{b,y}^{(j)}\) be the finite signed measure defined by \[\int_{\mathbb{R}^d} f(z)\,d\nu_{b,y}^{(j)}(z) = \int_{\mathbb{R}} \operatorname{sgn}(u)e^{-|u|/b} f(y+u e_j)\,du .\] A direct computation gives \[\varphi_{\nu_{b,y}^{(j)}}(\omega) = e^{i\omega^\top y} \frac{2ib^2\omega_j}{1+b^2\omega_j^2}.\] Therefore \[\mathcal{Q}_{j,V,y}(\omega) = y_j\varphi_{\delta_y}(\omega) + \varphi_{\nu_{b,y}^{(j)}}(\omega).\] Applying Proposition 4 entrywise gives \[\mathcal{T}_{j,V,y}[f] = y_j f(y)+(\mathsf D_{b,j}f)(y), \qquad f\in\mathcal{A}_V(\mathbb{R}^d).\] Hence, whenever \(f_Y(y)>0\), \[\boxed{ \mathbb{E}[X\mid Y=y] = y+ \frac{(\mathsf D_b f_Y)(y)}{f_Y(y)}. }\] Equivalently, for \(j=1,\ldots,d\), \[\mathbb{E}[X_j\mid Y=y] = y_j+ \frac{ \displaystyle \int_{\mathbb{R}} \operatorname{sgn}(u)e^{-|u|/b} f_Y(y+u e_j)\,du }{ f_Y(y) }.\]

Example 17 (Posterior second moment and covariance under product Laplace noise). Let \[g(x)=xx^\top .\] We apply the scalar representation entrywise to \(g_{jk}(x)=x_jx_k\). Define \[a_j(\omega) \mathrel{\mathop{:}}= \frac{2ib^2\omega_j}{1+b^2\omega_j^2}, \qquad a(\omega) \mathrel{\mathop{:}}= \bigl(a_1(\omega),\ldots,a_d(\omega)\bigr)^\top .\] The Fourier-domain representer for the second moment is \[\mathcal{Q}_{2,V,y}(\omega) = e^{i\omega^\top y} \left[ yy^\top + y a(\omega)^\top + a(\omega)y^\top + H(\omega) \right],\] where \[H_{jj}(\omega) = \frac{2b^2(1-3b^2\omega_j^2)}{(1+b^2\omega_j^2)^2}, \qquad H_{jk}(\omega) = a_j(\omega)a_k(\omega) \quad (j\neq k).\]

The first-order terms are represented by the signed measures \(\nu_{b,y}^{(j)}\) from Example 16. For the second-order terms, define signed measures \(\eta_{b,y}^{jk}\) by \[\int_{\mathbb{R}^d} f(z)\,d\eta_{b,y}^{jj}(z) = \int_{\mathbb{R}} (2|u|-b)e^{-|u|/b} f(y+u e_j)\,du,\] and, for \(j\neq k\), \[\int_{\mathbb{R}^d} f(z)\,d\eta_{b,y}^{jk}(z) = \int_{\mathbb{R}}\int_{\mathbb{R}} \operatorname{sgn}(u)\operatorname{sgn}(v) e^{-(|u|+|v|)/b} f(y+u e_j+v e_k)\,du\,dv .\] These measures satisfy \[\varphi_{\eta_{b,y}^{jk}}(\omega) = e^{i\omega^\top y}H_{jk}(\omega), \qquad 1\le j,k\le d.\] Thus Proposition 4 applies entrywise. For every \(f\in\mathcal{A}_V(\mathbb{R}^d)\), \[\mathcal{T}_{2,V,y}[f] = yy^\top f(y) + y(\mathsf D_b f)(y)^\top + (\mathsf D_b f)(y)y^\top + (\mathsf G_b f)(y).\] Taking \(f=f_Y\) and dividing by \(f_Y(y)\) gives the posterior second moment: \[\mathbb{E}[XX^\top\mid Y=y] = yy^\top + y\left(\frac{(\mathsf D_b f_Y)(y)}{f_Y(y)}\right)^\top + \left(\frac{(\mathsf D_b f_Y)(y)}{f_Y(y)}\right)y^\top + \frac{(\mathsf G_b f_Y)(y)}{f_Y(y)}.\] Combining this formula with Example 16, we obtain the covariance formula \[\boxed{ \operatorname{Cov}(X\mid Y=y) = \frac{(\mathsf G_b f_Y)(y)}{f_Y(y)} - \frac{ (\mathsf D_b f_Y)(y)(\mathsf D_b f_Y)(y)^\top }{ f_Y(y)^2 }. }\] Equivalently, coordinatewise, \[\operatorname{Cov}(X_j,X_k\mid Y=y) = \frac{(\mathsf G_{b,jk}f_Y)(y)}{f_Y(y)} - \frac{ (\mathsf D_{b,j}f_Y)(y)(\mathsf D_{b,k}f_Y)(y) }{ f_Y(y)^2 }.\]

Example 18 (Posterior moment generating function under product Laplace noise). Fix \(t\in\mathbb{R}^d\) with \[\|t\|_\infty<\frac{1}{b},\] and let \[g_t(x)=e^{t^\top x}.\] The restriction on \(t\) ensures that all kernels below are finite signed measures. Since the coordinates of \(V\) are independent Laplace random variables, the Fourier-domain representer factorizes coordinatewise: \[\mathcal{Q}_{g_t,V,y}(\omega) = e^{t^\top y}e^{i\omega^\top y} \prod_{j=1}^d \frac{1+b^2\omega_j^2}{1-b^2(t_j+i\omega_j)^2}.\]

For \(r\in(-1/b,1/b)\), define the finite signed measure \(\rho_{b,r}\) on \(\mathbb{R}\) by \[d\rho_{b,r}(u) = e^{ru} \left[ r\operatorname{sgn}(u)-\frac{b r^2}{2} \right] e^{-|u|/b}\,du .\] A direct calculation gives \[\int_{\mathbb{R}}e^{i\omega u}\,d\rho_{b,r}(u) = \frac{1+b^2\omega^2}{1-b^2(r+i\omega)^2}-1.\] Therefore, for each coordinate \(j\), \[\frac{1+b^2\omega_j^2}{1-b^2(t_j+i\omega_j)^2} = 1+ \int_{\mathbb{R}}e^{i\omega_j u}\,d\rho_{b,t_j}(u).\]

For a measurable function \(f:\mathbb{R}^d\to\mathbb{C}\), define \[(\mathsf M_{b,t}f)(y) \mathrel{\mathop{:}}= \sum_{S\subseteq\{1,\ldots,d\}} \int_{\mathbb{R}^{|S|}} f\!\left(y+\sum_{j\in S}u_j e_j\right) \prod_{j\in S}d\rho_{b,t_j}(u_j),\] where the term for \(S=\varnothing\) is interpreted as \(f(y)\). Expanding the coordinatewise product and applying Proposition 4 gives \[\mathcal{T}_{g_t,V,y}[f] = e^{t^\top y}(\mathsf M_{b,t}f)(y), \qquad f\in\mathcal{A}_V(\mathbb{R}^d).\] Hence, whenever \(f_Y(y)>0\), \[\boxed{ \mathbb{E}[e^{t^\top X}\mid Y=y] = e^{t^\top y} \frac{(\mathsf M_{b,t}f_Y)(y)}{f_Y(y)} . }\]

Equivalently, in expanded form, \[\mathbb{E}[e^{t^\top X}\mid Y=y] = \frac{e^{t^\top y}}{f_Y(y)} \sum_{S\subseteq\{1,\ldots,d\}} \int_{\mathbb{R}^{|S|}} f_Y\!\left(y+\sum_{j\in S}u_j e_j\right) \prod_{j\in S}d\rho_{b,t_j}(u_j).\]

1.0.1.5.3.2 Loss functionals in the one-dimensional Laplace mechanism

We now specialize to \(d=1\) and \[V\sim \mathrm{Laplace}(0,b).\]

For the loss formulas below, it is useful to introduce \[(\mathsf K_b f)(y) \mathrel{\mathop{:}}= \int_{\mathbb{R}}e^{-|u|/b}f(y+u)\,du,\] \[(\mathsf K_b^+ f)(y) \mathrel{\mathop{:}}= \int_0^\infty e^{-u/b}f(y+u)\,du, \qquad (\mathsf K_b^- f)(y) \mathrel{\mathop{:}}= \int_{-\infty}^0 e^{u/b}f(y+u)\,du.\] For \(a,y\in\mathbb{R}\), define the interval correction \[(\mathsf J_{b,a}f)(y) \mathrel{\mathop{:}}= \int_{\min(0,a-y)}^{\max(0,a-y)} e^{-|u|/b}f(y+u)\,du,\] and the boundary correction \[(\mathsf R_{b,a}f)(y) \mathrel{\mathop{:}}= b e^{-|y-a|/b}f(a).\]

Example 19 (Posterior distribution function under one-dimensional Laplace noise). Assume \(d=1\), and let \[g_a(x)=\mathbf{1}_{\{x\le a\}}, \qquad a\in\mathbb{R} .\] This functional is easier to compute directly than through Fourier inversion. Define \[A(a) \mathrel{\mathop{:}}= \int_{x\le a} f_V(a-x)\,dP_X(x), \qquad B(a) \mathrel{\mathop{:}}= \int_{x>a} f_V(a-x)\,dP_X(x).\] Then \[f_Y(a)=A(a)+B(a).\]

The Laplace density is not differentiable at the origin, so we use the right derivative \[D_+f_Y(a) \mathrel{\mathop{:}}= \lim_{h\downarrow0} \frac{f_Y(a+h)-f_Y(a)}{h}.\] This derivative exists. Indeed, the Laplace density is Lipschitz, and its right derivative at \(a-x\) is \[D_+ f_V(a-x) = \begin{cases} -\dfrac1b f_V(a-x), & x\le a, \\[0.8em] \phantom{-}\dfrac1b f_V(a-x), & x>a . \end{cases}\] Dominated convergence therefore gives \[D_+f_Y(a) = -\frac{1}{b} A(a)+\frac{1}{b} B(a).\] Solving the two equations \[f_Y(a)=A(a)+B(a), \qquad D_+f_Y(a)=-\frac{1}{b} A(a)+\frac{1}{b} B(a),\] yields \[A(a) = \frac{1}{2}\{f_Y(a)-bD_+f_Y(a)\}, \qquad B(a) = \frac{1}{2}\{f_Y(a)+bD_+f_Y(a)\}.\]

Define the lower and upper Laplace tail functionals \[L_b^-(a) \mathrel{\mathop{:}}= \frac{1}{2}\{f_Y(a)-bD_+f_Y(a)\}, \qquad L_b^+(a) \mathrel{\mathop{:}}= \frac{1}{2}\{f_Y(a)+bD_+f_Y(a)\}.\] Thus \(L_b^-(a)=A(a)\) and \(L_b^+(a)=B(a)\).

Now fix \(y\) with \(f_Y(y)>0\). If \(a\le y\), then for \(x\le a\), \[f_V(y-x) = e^{-(y-a)/b}f_V(a-x).\] Hence \[\int_{x\le a} f_V(y-x)\,dP_X(x) = e^{-(y-a)/b}L_b^-(a).\] If \(a>y\), it is shorter to compute the upper tail. For \(x>a\), \[f_V(y-x) = e^{-(a-y)/b}f_V(a-x),\] so \[\int_{x>a} f_V(y-x)\,dP_X(x) = e^{-(a-y)/b}L_b^+(a).\] Therefore \[\boxed{ \mathbb{P}(X\le a\mid Y=y) = \begin{cases} \displaystyle \dfrac{e^{-(y-a)/b}L_b^-(a)}{f_Y(y)}, & a\le y, \\[1.2em] \displaystyle 1- \dfrac{e^{-(a-y)/b}L_b^+(a)}{f_Y(y)}, & a>y . \end{cases} }\] Equivalently, \[L_b^-(a)=\frac{1}{2}\{f_Y(a)-bD_+f_Y(a)\}, \qquad L_b^+(a)=\frac{1}{2}\{f_Y(a)+bD_+f_Y(a)\}.\]

Example 20 (Posterior squared risk under Laplace noise). Fix \(a\in\mathbb{R}\). Expanding the square gives \[\mathbb{E}[(X-a)^2\mid Y=y] = \mathbb{E}[X^2\mid Y=y] - 2a\,\mathbb{E}[X\mid Y=y] + a^2.\] Substituting the posterior first and second moment formulas yields \[\boxed{ \mathbb{E}[(X-a)^2\mid Y=y] = (y-a)^2 + 2(y-a)\frac{(\mathsf D_b f_Y)(y)}{f_Y(y)} + \frac{(\mathsf G_b f_Y)(y)}{f_Y(y)}. }\] Equivalently, \[\begin{align} \mathbb{E}[(X-a)^2\mid Y=y] &= (y-a)^2 \\ &\quad+ \frac{2(y-a)}{f_Y(y)} \int_{\mathbb{R}} \operatorname{sgn}(u)e^{-|u|/b}f_Y(y+u)\,du \\ &\quad+ \frac{1}{f_Y(y)} \int_{\mathbb{R}} (2|u|-b)e^{-|u|/b}f_Y(y+u)\,du . \end{align}\]

Example 21 (Posterior absolute risk under Laplace noise). Fix \(a\in\mathbb{R}\), and let \[F_y(t) \mathrel{\mathop{:}}= \mathbb{P}(X\le t\mid Y=y).\] The identity \[\mathbb{E}[|X-a|\mid Y=y] = \int_{-\infty}^{a}F_y(t)\,dt + \int_a^\infty \{1-F_y(t)\}\,dt\] combined with the posterior distribution formula from Example 19 gives \[\mathbb{E}[|X-a|\mid Y=y] = |y-a| + \frac{1}{f_Y(y)} \left[ \int_{\mathbb{R}} \operatorname{sgn}(u)\operatorname{sgn}(y+u-a) e^{-|u|/b}f_Y(y+u)\,du - (\mathsf R_{b,a}f_Y)(y) \right].\] Since \[\operatorname{sgn}(u)\operatorname{sgn}(u-(a-y)) = 1\] outside the interval between \(0\) and \(a-y\), and equals \(-1\) inside that interval, this becomes \[\boxed{ \mathbb{E}[|X-a|\mid Y=y] = |y-a| + \frac{ (\mathsf K_b f_Y)(y) - 2(\mathsf J_{b,a}f_Y)(y) - (\mathsf R_{b,a}f_Y)(y) }{ f_Y(y) }. }\] In expanded form, \[\begin{align} \mathbb{E}[|X-a|\mid Y=y] &= |y-a| + \frac{1}{f_Y(y)} \bigg[ \int_{\mathbb{R}} e^{-|u|/b}f_Y(y+u)\,du \\ &\qquad - 2 \int_{\min(0,a-y)}^{\max(0,a-y)} e^{-|u|/b}f_Y(y+u)\,du - b e^{-|y-a|/b}f_Y(a) \bigg]. \end{align}\]

Example 22 (Posterior hinge loss under Laplace noise). Fix \(a\in\mathbb{R}\). Since \[(x-a)_+ = \frac{1}{2}|x-a|+\frac{1}{2}(x-a),\] we have \[\mathbb{E}[(X-a)_+\mid Y=y] = \frac{1}{2}\mathbb{E}[|X-a|\mid Y=y] + \frac{1}{2}\{\mathbb{E}[X\mid Y=y]-a\}.\] Substituting the posterior mean and absolute-risk formulas gives \[\boxed{ \mathbb{E}[(X-a)_+\mid Y=y] = (y-a)_+ + \frac{ (\mathsf K_b^+ f_Y)(y) - (\mathsf J_{b,a}f_Y)(y) - \frac{1}{2}(\mathsf R_{b,a}f_Y)(y) }{ f_Y(y) }. }\] Equivalently, \[\begin{align} \mathbb{E}[(X-a)_+\mid Y=y] &= (y-a)_+ + \frac{1}{f_Y(y)} \int_0^\infty e^{-u/b}f_Y(y+u)\,du \\ &\quad - \frac{1}{f_Y(y)} \int_{\min(0,a-y)}^{\max(0,a-y)} e^{-|u|/b}f_Y(y+u)\,du \\ &\quad - \frac{b e^{-|y-a|/b}f_Y(a)}{2f_Y(y)}. \end{align}\]

Example 23 (Posterior pinball loss under Laplace noise). Fix \(a\in\mathbb{R}\) and \(\tau\in(0,1)\). Let \[\rho_\tau(z) = \tau z_+ + (1-\tau)(-z)_+ .\] Then \[\rho_\tau(X-a) = \tau(X-a)_+ + (1-\tau)(a-X)_+.\] Using the hinge formula for both \((X-a)_+\) and \((a-X)_+\) gives \[\boxed{ \begin{align} \mathbb{E}[\rho_\tau(X-a)\mid Y=y] &= \tau(y-a)_+ + (1-\tau)(a-y)_+ \\ &\quad+ \frac{ \tau(\mathsf K_b^+ f_Y)(y) + (1-\tau)(\mathsf K_b^- f_Y)(y) - (\mathsf J_{b,a}f_Y)(y) - \frac{1}{2}(\mathsf R_{b,a}f_Y)(y) }{ f_Y(y) }. \end{align} }\] In expanded form, \[\begin{align} \mathbb{E}[\rho_\tau(X-a)\mid Y=y] &= \tau(y-a)_+ + (1-\tau)(a-y)_+ \\ &\quad+ \frac{\tau}{f_Y(y)} \int_0^\infty e^{-u/b}f_Y(y+u)\,du \\ &\quad+ \frac{1-\tau}{f_Y(y)} \int_{-\infty}^0 e^{u/b}f_Y(y+u)\,du \\ &\quad- \frac{1}{f_Y(y)} \int_{\min(0,a-y)}^{\max(0,a-y)} e^{-|u|/b}f_Y(y+u)\,du \\ &\quad- \frac{b e^{-|y-a|/b}f_Y(a)}{2f_Y(y)} . \end{align}\]

1.0.1.5.4 Gaussian approximation to posterior distribution functions

The next lemma gives an explicit derivative expansion for a smooth approximation to the posterior distribution function.

Lemma 6 (Explicit form of the approximating functional for the posterior cdf). Fix \(n\ge1\), \(x,y\in\mathbb{R}\), and \(\sigma>0\). Suppose \(d=1\) and \[V\sim \mathcal{N}(0,\sigma^2).\] Define \[g_{n,x}(u) \mathrel{\mathop{:}}= \Phi\left( \frac{x+n^{-1/2}-u}{n^{-1}} \right), \qquad u\in\mathbb{R}.\] Set \[s_n\mathrel{\mathop{:}}=\sqrt{\sigma^2+n^{-2}}, \qquad a_n\mathrel{\mathop{:}}=\frac{x+n^{-1/2}-y}{s_n}.\] Then, for every \(f\in\mathcal{A}_V(\mathbb{R})\), \[\mathcal{T}_{g_{n,x},V,y}[f] = \sum_{k=0}^{\infty} \frac{(-1)^k}{k!} \left(\frac{\sigma^2}{s_n}\right)^k \Phi^{(k)}(a_n) f^{(k)}(y).\] For each fixed \(n\), the series converges absolutely.

Proof. Let \[\rho_n\mathrel{\mathop{:}}=\frac{\sigma}{s_n}.\] Since \(n\ge1\), we have \(0<\rho_n<1\). We use the probabilists’ Hermite polynomials \[\operatorname{He}_k(z) = (-1)^k e^{z^2/2} \frac{d^k}{dz^k}e^{-z^2/2}, \qquad z\in\mathbb{R}.\]

Step 1: Hermite expansion of the smooth cdf. For \(u\in\mathbb{R}\), set \[z=\frac{y-u}{\sigma}.\] Then \[\frac{x+n^{-1/2}-u}{n^{-1}} = \frac{a_n+\rho_n z}{\sqrt{1-\rho_n^2}}.\] Mehler’s formula gives, for \(|\rho|<1\), \[\frac{\phi_{-\rho}(w,z)}{\phi(w)\phi(z)} = \sum_{k=0}^{\infty} \frac{(-\rho)^k}{k!} \operatorname{He}_k(w)\operatorname{He}_k(z),\] where \(\phi_{-\rho}\) is the standard bivariate normal density with correlation \(-\rho\); see [77], Theorem 4.7.2. Therefore \[\int_{-\infty}^{a} \frac{\phi_{-\rho}(w,z)}{\phi(z)}\,dw = \Phi\left(\frac{a+\rho z}{\sqrt{1-\rho^2}}\right).\]

We justify termwise integration. By Cramer’s bound for Hermite polynomials, there is a constant \(C>0\) such that \[|\operatorname{He}_k(r)| \le C e^{r^2/4}\sqrt{k!}, \qquad r\in\mathbb{R},\quad k\ge0;\] see [76], Formula 22.14.17. Hence, for fixed \(z\in\mathbb{R}\), \[\phi(w) \left| \frac{(-\rho)^k}{k!} \operatorname{He}_k(w)\operatorname{He}_k(z) \right| \le C^2 e^{z^2/4}\rho^k e^{-w^2/4}.\] Since \(\sum_{k\ge0}\rho^k<\infty\) and \(e^{-w^2/4}\) is integrable on \((-\infty,a]\), Fubini’s theorem gives \[\int_{-\infty}^{a} \frac{\phi_{-\rho}(w,z)}{\phi(z)}\,dw = \sum_{k=0}^{\infty} \frac{(-\rho)^k}{k!} \operatorname{He}_k(z) \int_{-\infty}^{a} \operatorname{He}_k(w)\phi(w)\,dw .\]

For \(k\ge1\), Rodrigues’ formula implies \[\operatorname{He}_k(w)\phi(w) = (-1)^k\phi^{(k)}(w).\] Thus \[\int_{-\infty}^{a} \operatorname{He}_k(w)\phi(w)\,dw = (-1)^k\phi^{(k-1)}(a) = (-1)^k\Phi^{(k)}(a).\] The same identity holds for \(k=0\), with \(\Phi^{(0)}=\Phi\). Therefore \[\Phi\left(\frac{a+\rho z}{\sqrt{1-\rho^2}}\right) = \sum_{k=0}^{\infty} \frac{\rho^k}{k!} \Phi^{(k)}(a)\operatorname{He}_k(z).\] Taking \(a=a_n\), \(\rho=\rho_n\), and \(z=(y-u)/\sigma\), we obtain \[g_{n,x}(u) = \sum_{k=0}^{\infty} \frac{\rho_n^k}{k!} \Phi^{(k)}(a_n) \operatorname{He}_k\!\left(\frac{y-u}{\sigma}\right).\]

Step 2: finite approximants. For \(M\ge0\), define \[g_{n,M,x,y}(u) \mathrel{\mathop{:}}= \sum_{k=0}^{M} \frac{\rho_n^k}{k!} \Phi^{(k)}(a_n) \operatorname{He}_k\!\left(\frac{y-u}{\sigma}\right).\] Let \[\lambda_{n,M,x,y}(u) \mathrel{\mathop{:}}= g_{n,M,x,y}(u)f_V(y-u), \qquad \lambda_{n,x,y}(u) \mathrel{\mathop{:}}= g_{n,x}(u)f_V(y-u).\] We now show that \[\lambda_{n,M,x,y}\to \lambda_{n,x,y} \qquad \text{uniformly on }\mathbb{R} .\]

Since \[f_V(y-u) = \frac{1}{\sigma}\phi\!\left(\frac{y-u}{\sigma}\right),\] it is enough to bound the terms \[\frac{1}{\sigma}\phi(z) \frac{\rho_n^k}{k!} \Phi^{(k)}(a_n)\operatorname{He}_k(z).\] For \(k\ge1\), \[\Phi^{(k)}(a_n) = \phi^{(k-1)}(a_n) = (-1)^{k-1} \operatorname{He}_{k-1}(a_n)\phi(a_n).\] Cramer’s bound gives \[|\Phi^{(k)}(a_n)| \le \frac{C}{\sqrt{2\pi}} e^{-a_n^2/4}\sqrt{(k-1)!}.\] Hence, uniformly in \(z\in\mathbb{R}\), \[\frac{1}{\sigma}\phi(z) \frac{\rho_n^k}{k!} |\Phi^{(k)}(a_n)| |\operatorname{He}_k(z)| \le \frac{C^2}{2\pi\sigma} e^{-a_n^2/4} \frac{\rho_n^k}{\sqrt{k}}.\] Since \[\sum_{k=1}^{\infty}\frac{\rho_n^k}{\sqrt{k}}<\infty,\] the Weierstrass \(M\)-test gives uniform absolute convergence; see [78], Theorem 7.10. Thus \[\lambda_{n,M,x,y}\to \lambda_{n,x,y} \quad \text{uniformly,}\] and \[\sup_{M\ge0} \|\lambda_{n,M,x,y}\|_\infty <\infty .\] Moreover, each \(\lambda_{n,M,x,y}\) is a finite sum of polynomials times a Gaussian density, and therefore belongs to \(C_0(\mathbb{R};\mathbb{C})\).

By Proposition 3, applied with \(M\) as the approximation index, \[\mathcal{T}_{g_{n,x},V,y}[f] = \lim_{M\to\infty} \mathcal{T}_{n,M,x,y}[f], \qquad f\in\mathcal{A}_V(\mathbb{R}),\] where \(\mathcal{T}_{n,M,x,y}\) denotes the Tweedie functional generated by \(g_{n,M,x,y}\) at the point \(y\).

Step 3: explicit calculation for the finite approximants. For the Gaussian density, \[\frac{d^k}{du^k}f_V(y-u) = \frac{1}{\sigma^k} \operatorname{He}_k\!\left(\frac{y-u}{\sigma}\right) f_V(y-u).\] Therefore \[\operatorname{He}_k\!\left(\frac{y-u}{\sigma}\right)f_V(y-u) = \sigma^k\frac{d^k}{du^k}f_V(y-u).\] Using the Fourier convention of the paper, \[\widetilde{\frac{d^k}{du^k}f_V(y-\cdot)}(\omega) = (-i\omega)^k e^{i\omega y}e^{-\sigma^2\omega^2/2}.\] Since \(\varphi_V(-\omega)=e^{-\sigma^2\omega^2/2}\), the Fourier-domain representer for \(\lambda_{n,M,x,y}\) is \[\mathcal{Q}_{n,M,x,y}(\omega) = \sum_{k=0}^{M} \frac{1}{k!} \left( -\frac{\sigma^2}{s_n} \right)^k \Phi^{(k)}(a_n) (i\omega)^k e^{i\omega y}.\] Thus Proposition 4, applied with smoothness order \(M\), gives \[\mathcal{T}_{n,M,x,y}[f] = \sum_{k=0}^{M} \frac{1}{k!} \left( -\frac{\sigma^2}{s_n} \right)^k \Phi^{(k)}(a_n) f^{(k)}(y).\]

Letting \(M\to\infty\) yields \[\mathcal{T}_{g_{n,x},V,y}[f] = \sum_{k=0}^{\infty} \frac{(-1)^k}{k!} \left(\frac{\sigma^2}{s_n}\right)^k \Phi^{(k)}(a_n) f^{(k)}(y),\] provided the series is absolutely convergent. We prove this next.

Step 4: absolute convergence. Write \[f=f_V*\mu, \qquad \mu\in\mathcal{M}(\mathbb{R}).\] Since all derivatives of the Gaussian density are bounded and continuous, differentiation under the integral gives \[f^{(k)}(y) = \int_{\mathbb{R}} f_V^{(k)}(y-u)\,d\mu(u).\] By Rodrigues’ formula, \[f_V^{(k)}(y-u) = \frac{(-1)^k}{\sigma^k} \operatorname{He}_k\!\left(\frac{y-u}{\sigma}\right) f_V(y-u).\] Thus \[f^{(k)}(y) = \frac{(-1)^k}{\sigma^k} \int_{\mathbb{R}} \operatorname{He}_k\!\left(\frac{y-u}{\sigma}\right) f_V(y-u)\,d\mu(u).\] Consequently, \[\begin{align} &\left| \frac{(-1)^k}{k!} \left(\frac{\sigma^2}{s_n}\right)^k \Phi^{(k)}(a_n)f^{(k)}(y) \right| \\ &\qquad\le \int_{\mathbb{R}} \frac{1}{\sigma} \phi\!\left(\frac{y-u}{\sigma}\right) \frac{\rho_n^k}{k!} |\Phi^{(k)}(a_n)| \left| \operatorname{He}_k\!\left(\frac{y-u}{\sigma}\right) \right| \,d|\mu|(u). \end{align}\] The uniform bound from Step 2 gives, for \(k\ge1\), \[\left| \frac{(-1)^k}{k!} \left(\frac{\sigma^2}{s_n}\right)^k \Phi^{(k)}(a_n)f^{(k)}(y) \right| \le C_n\frac{\rho_n^k}{\sqrt{k}}\|\mu\|_{TV},\] where \(C_n<\infty\) does not depend on \(k\). Since \[\sum_{k=1}^{\infty}\frac{\rho_n^k}{\sqrt{k}}<\infty,\] the derivative series converges absolutely for each fixed \(n\). The \(k=0\) term is finite, so the proof is complete. ◻

1.0.1.5.5 Functionals under the heteroskedastic Gaussian sequence model

This section records several Tweedie formulas for the heteroskedastic Gaussian sequence model.

1.0.1.5.5.1 Functionals in the multi-dimensional Gaussian model

Fix \[\Sigma_0\in\mathbb{S}_{++}^d, \qquad y\in\mathbb{R}^d,\] and write \[B\mathrel{\mathop{:}}=\Sigma_0^{1/2}, \qquad z_0\mathrel{\mathop{:}}=B^{-1}y.\] We work in the standardized model \[Z=W+V, \qquad V\sim\mathcal{N}(0,I_d),\] from Proposition 5. Let \[f_Z(z) \mathrel{\mathop{:}}= f_{Z\mid\Sigma}(z\mid\Sigma_0), \qquad f_{\Sigma_0}(u) \mathrel{\mathop{:}}= f_{Y\mid\Sigma}(u\mid\Sigma_0).\] Then \[f_Z(z) = \det(B)\,f_{\Sigma_0}(Bz).\]

We use the following elementary Gaussian Fourier identities. Let \[h_{z_0}(w)\mathrel{\mathop{:}}=\phi(z_0-w).\] Since \[\widetilde{h}_{z_0}(\omega) = e^{i\omega^\top z_0}e^{-\|\omega\|_2^2/2},\] and \[\varphi_V(-\omega)=e^{-\|\omega\|_2^2/2},\] we have \[\frac{\widetilde{B w h_{z_0}}(\omega)}{\varphi_V(-\omega)} = e^{i\omega^\top z_0}(y+iB\omega),\] and \[\frac{\widetilde{Bww^\top B h_{z_0}}(\omega)}{\varphi_V(-\omega)} = e^{i\omega^\top z_0} B\{(z_0+i\omega)(z_0+i\omega)^\top+I_d\}B .\] Equivalently, \[e^{i\omega^\top z_0} B\{(z_0+i\omega)(z_0+i\omega)^\top+I_d\}B = e^{i\omega^\top z_0} \left[ yy^\top+\Sigma_0 +i\,y(B\omega)^\top +i\,(B\omega)y^\top -B\omega\omega^\top B \right].\]

Example 24 (Posterior mean). Let \[g(x)=x.\] The Fourier-domain representer is \[\mathcal{Q}_{g,y,\Sigma_0}(\omega) = e^{i\omega^\top z_0}(y+iB\omega).\] This is a finite linear combination of \[\varphi_{\delta_{z_0}}(\omega) \quad\text{and}\quad (i\omega_\ell)\varphi_{\delta_{z_0}}(\omega), \qquad \ell=1,\ldots,d.\] Therefore Proposition 4 applies coordinatewise with smoothness order \(1\), and gives \[\mathcal{T}_{g,y,\Sigma_0}[f] = y f(z_0)+B\nabla f(z_0), \qquad f\in\mathcal{A}_V(\mathbb{R}^d).\] Taking \(f=f_Z\) yields \[\mathbb{E}[X\mid Y=y,\Sigma=\Sigma_0] = y+B\nabla_z\log f_Z(z_0).\] Since \[\nabla_z\log f_Z(z_0) = B\nabla_y\log f_{\Sigma_0}(y),\] we obtain the usual heteroskedastic Tweedie formula: \[\boxed{ \mathbb{E}[X\mid Y=y,\Sigma=\Sigma_0] = y+\Sigma_0\nabla_y\log f_{\Sigma_0}(y). }\]

Example 25 (Posterior covariance). Let \[g(x)=xx^\top.\] The Fourier-domain representer is \[\mathcal{Q}_{g,y,\Sigma_0}(\omega) = e^{i\omega^\top z_0} \left[ yy^\top+\Sigma_0 +i\,y(B\omega)^\top +i\,(B\omega)y^\top -B\omega\omega^\top B \right].\] This symbol is a finite linear combination of \[\varphi_{\delta_{z_0}}(\omega), \qquad (i\omega_\ell)\varphi_{\delta_{z_0}}(\omega), \qquad (i\omega_\ell)(i\omega_m)\varphi_{\delta_{z_0}}(\omega).\] Thus Proposition 4 applies entrywise with smoothness order \(2\), and gives \[\begin{align} \mathcal{T}_{g,y,\Sigma_0}[f] &= (yy^\top+\Sigma_0)f(z_0) \\ &\quad + y\{B\nabla f(z_0)\}^\top + \{B\nabla f(z_0)\}y^\top + B\nabla^2 f(z_0)B . \end{align}\] Taking \(f=f_Z\), dividing by \(f_Z(z_0)\), and subtracting the outer product of the posterior mean from Example 24 gives \[\operatorname{Var}(X\mid Y=y,\Sigma=\Sigma_0) = \Sigma_0 + B\nabla_z^2\log f_Z(z_0)B.\] Since \[\nabla_z^2\log f_Z(z_0) = B\nabla_y^2\log f_{\Sigma_0}(y)B,\] we obtain \[\boxed{ \operatorname{Var}(X\mid Y=y,\Sigma=\Sigma_0) = \Sigma_0 + \Sigma_0\nabla_y^2\log f_{\Sigma_0}(y)\Sigma_0 . }\]

Example 26 (Posterior moment generating function). Fix \(t\in\mathbb{R}^d\), and let \[g_t(x)=e^{t^\top x}.\] Then \[\lambda_{g_t,y,\Sigma_0}(w) = e^{t^\top Bw}\phi(z_0-w).\] Completing the square gives \[e^{t^\top Bw}\phi(z_0-w) = \exp\!\left(t^\top y+\frac{1}{2} t^\top\Sigma_0 t\right) \phi(z_0+Bt-w).\] Therefore \[\mathcal{Q}_{g_t,y,\Sigma_0}(\omega) = \exp\!\left(t^\top y+\frac{1}{2} t^\top\Sigma_0 t\right) e^{i\omega^\top(z_0+Bt)}.\] Proposition 4 applies with smoothness order \(0\), represented by the measure \[\mu_0 = \exp\!\left(t^\top y+\frac{1}{2} t^\top\Sigma_0 t\right) \delta_{z_0+Bt}.\] Thus \[\mathcal{T}_{g_t,y,\Sigma_0}[f] = \exp\!\left(t^\top y+\frac{1}{2} t^\top\Sigma_0 t\right) f(z_0+Bt).\] Taking \(f=f_Z\) gives \[\mathbb{E}[e^{t^\top X}\mid Y=y,\Sigma=\Sigma_0] = \exp\!\left(t^\top y+\frac{1}{2} t^\top\Sigma_0 t\right) \frac{f_Z(z_0+Bt)}{f_Z(z_0)}.\] Changing back to the original \(Y\)-scale, \[\boxed{ \mathbb{E}[e^{t^\top X}\mid Y=y,\Sigma=\Sigma_0] = \exp\!\left(t^\top y+\frac{1}{2} t^\top\Sigma_0 t\right) \frac{f_{\Sigma_0}(y+\Sigma_0 t)}{f_{\Sigma_0}(y)}. }\]

1.0.1.5.5.2 Functionals in the one-dimensional Gaussian model

Assume \(d=1\), write \[\Sigma_0=\sigma^2, \qquad \sigma>0,\] and set \[f_\sigma(u) \mathrel{\mathop{:}}= f_{Y\mid\Sigma}(u\mid\sigma^2), \qquad f_\sigma^{(k)}(u) \mathrel{\mathop{:}}= \partial_u^k f_{Y\mid\Sigma}(u\mid\sigma^2).\] All formulas below are stated for points \(y\) such that \[f_\sigma(y)>0.\]

For \(n\ge1\) and \(c\in\mathbb{R}\), define \[s_n \mathrel{\mathop{:}}= \sqrt{\sigma^2+n^{-2}}, \qquad q_{n,c} \mathrel{\mathop{:}}= \frac{c+n^{-1/2}-y}{s_n}, \qquad q_c \mathrel{\mathop{:}}= \frac{c-y}{\sigma}.\] We use the convention \(\Phi^{(0)}=\Phi\). For \(r\in\{0,1\}\) and \(m\ge r\), define the Gaussian series operator \[\mathsf S_{n,c}^{(r,m)}[f](y) \mathrel{\mathop{:}}= \sum_{k=m}^{\infty} \frac{(-1)^k}{k!} \left(\frac{\sigma^2}{s_n}\right)^k s_n^r \Phi^{(k-r)}(q_{n,c}) f^{(k)}(y).\] For each fixed \(n\), the series is absolutely convergent in the cases used below by Lemma 6. The parameter \(r\) records how many times the smoothed cdf has been integrated: \(r=0\) gives the cdf series, while \(r=1\) gives the integrated series used for hinge losses.

We also define \[\mathsf A_{n,c}(y) \mathrel{\mathop{:}}= s_n\{q_{n,c}\Phi(q_{n,c})+\phi(q_{n,c})\}.\] This is the zeroth-order term that appears when the smoothed cdf is integrated over \((-\infty,c]\).

Example 27 (Posterior moments in dimension one). Assume \(d=1\), and write \[\Sigma_0=\sigma^2, \qquad \sigma>0.\] Let \[f_\sigma(u) \mathrel{\mathop{:}}= f_{Y\mid\Sigma}(u\mid\sigma^2).\] By Example 26, \[\mathbb{E}[e^{tX}\mid Y=y,\Sigma=\sigma^2] = \exp\!\left(ty+\frac{1}{2}\sigma^2t^2\right) \frac{f_\sigma(y+\sigma^2t)}{f_\sigma(y)}.\]

For \(m\ge0\), define \[\mathsf H_m(a,\sigma^2) \mathrel{\mathop{:}}= \left. \frac{d^m}{dt^m} \exp\!\left(at+\frac{1}{2}\sigma^2t^2\right) \right|_{t=0}.\] Equivalently, \[\mathsf H_m(a,\sigma^2) = \sum_{j=0}^{\lfloor m/2\rfloor} \frac{m!}{2^j j!(m-2j)!} \sigma^{2j}a^{m-2j}.\] Differentiating the posterior moment generating function at \(t=0\) gives \[\boxed{ \mathbb{E}[X^m\mid Y=y,\Sigma=\sigma^2] = \sum_{r=0}^{m} \binom{m}{r} \sigma^{2r} \mathsf H_{m-r}(y,\sigma^2) \frac{f_\sigma^{(r)}(y)}{f_\sigma(y)}. }\]

Now let \[\kappa(y,\sigma^2) \mathrel{\mathop{:}}= \mathbb{E}[X\mid Y=y,\Sigma=\sigma^2] = y+\sigma^2\frac{f_\sigma'(y)}{f_\sigma(y)}.\] The centered posterior moment follows by replacing \(y\) with \(y-\kappa(y,\sigma^2)\) in the exponential factor: \[\boxed{ \mathbb{E}\!\left[ \{X-\kappa(y,\sigma^2)\}^m \mid Y=y,\Sigma=\sigma^2 \right] = \sum_{r=0}^{m} \binom{m}{r} \sigma^{2r} \mathsf H_{m-r}(y-\kappa(y,\sigma^2),\sigma^2) \frac{f_\sigma^{(r)}(y)}{f_\sigma(y)}. }\]

Example 28 (Posterior even-power risk in dimension one). Assume \(d=1\), write \[\Sigma_0=\sigma^2, \qquad \sigma>0,\] and fix \(a\in\mathbb{R}\). Let \(q=2m\), where \(m\in\mathbb{N}\). Since \[|X-a|^{2m}=(X-a)^{2m},\] we differentiate the shifted posterior moment generating function \[\mathbb{E}[e^{t(X-a)}\mid Y=y,\Sigma=\sigma^2] = \exp\!\left((y-a)t+\frac{1}{2}\sigma^2t^2\right) \frac{f_\sigma(y+\sigma^2t)}{f_\sigma(y)}.\] Using the polynomial \(\mathsf H_m\) from Example 27, we obtain \[\boxed{ \mathbb{E}[|X-a|^{2m}\mid Y=y,\Sigma=\sigma^2] = \sum_{r=0}^{2m} \binom{2m}{r} \sigma^{2r} \mathsf H_{2m-r}(y-a,\sigma^2) \frac{f_\sigma^{(r)}(y)}{f_\sigma(y)}. }\]

Example 29 (Posterior distribution function). Fix \(x\in\mathbb{R}\). For \(n\ge1\), define \[g_{n,x}(u) \mathrel{\mathop{:}}= \Phi\left( \frac{x+n^{-1/2}-u}{n^{-1}} \right).\] Then \[g_{n,x}(u)\to \mathbf{1}_{\{u\le x\}} \qquad \text{for every }u\in\mathbb{R}.\] By Lemma 6, \[\mathcal{T}_{g_{n,x},V,y}[f_\sigma] = \mathsf S_{n,x}^{(0,0)}[f_\sigma](y).\] Separating the zeroth term gives \[\mathsf S_{n,x}^{(0,0)}[f_\sigma](y) = \Phi(q_{n,x})f_\sigma(y) + \mathsf S_{n,x}^{(0,1)}[f_\sigma](y).\] Since \(0\le g_{n,x}\le1\), dominated convergence gives \[\boxed{ \mathbb{P}(X\le x\mid Y=y,\Sigma=\sigma^2) = \Phi(q_x) + \frac{1}{f_\sigma(y)} \lim_{n\to\infty} \mathsf S_{n,x}^{(0,1)}[f_\sigma](y). }\] Equivalently, \[\mathbb{P}(X\le x\mid Y=y,\Sigma=\sigma^2) = \Phi\left(\frac{x-y}{\sigma}\right) + \frac{1}{f_\sigma(y)} \lim_{n\to\infty} \sum_{k=1}^{\infty} \frac{(-1)^k}{k!} \left(\frac{\sigma^2}{s_n}\right)^k \Phi^{(k)}(q_{n,x}) f_\sigma^{(k)}(y).\]

Example 30 (Posterior left hinge). Fix \(a\in\mathbb{R}\). We first compute the left hinge \[(a-X)_+.\] For \(n\ge1\), define \[\ell_{n,a}(u) \mathrel{\mathop{:}}= \int_{-\infty}^{a} \Phi\left( \frac{t+n^{-1/2}-u}{n^{-1}} \right)dt .\] Then \[\ell_{n,a}(u)\to(a-u)_+ \qquad \text{for every }u\in\mathbb{R}.\] Moreover, \(\ell_{n,a}(u)\phi_\sigma(y-u)\) is continuous, vanishes at infinity, and is uniformly bounded in \(n\). Hence Proposition 3 applies.

Integrating the expansion in Lemma 6 over \(t\le a\) gives \[\mathcal{T}_{\ell_{n,a},V,y}[f_\sigma] = \mathsf A_{n,a}(y)f_\sigma(y) + \mathsf S_{n,a}^{(1,1)}[f_\sigma](y).\] Since \[\mathsf S_{n,a}^{(1,1)}[f_\sigma](y) = -\sigma^2\Phi(q_{n,a})f_\sigma'(y) + \mathsf S_{n,a}^{(1,2)}[f_\sigma](y),\] we obtain \[\mathcal{T}_{\ell_{n,a},V,y}[f_\sigma] = \mathsf A_{n,a}(y)f_\sigma(y) - \sigma^2\Phi(q_{n,a})f_\sigma'(y) + \mathsf S_{n,a}^{(1,2)}[f_\sigma](y).\] Letting \(n\to\infty\) yields \[\boxed{ \mathbb{E}[(a-X)_+\mid Y=y,\Sigma=\sigma^2] = \sigma\{q_a\Phi(q_a)+\phi(q_a)\} - \sigma^2\Phi(q_a) \frac{f_\sigma'(y)}{f_\sigma(y)} + \frac{1}{f_\sigma(y)} \lim_{n\to\infty} \mathsf S_{n,a}^{(1,2)}[f_\sigma](y). }\]

Example 31 (Posterior right hinge). Fix \(a\in\mathbb{R}\). Since \[(X-a)_+ = X-a+(a-X)_+,\] we combine Example 30 with the Gaussian Tweedie formula \[\mathbb{E}[X\mid Y=y,\Sigma=\sigma^2] = y+\sigma^2\frac{f_\sigma'(y)}{f_\sigma(y)}.\] This gives \[\boxed{ \begin{align} \mathbb{E}[(X-a)_+\mid Y=y,\Sigma=\sigma^2] &= \sigma\phi(q_a) + (y-a)\{1-\Phi(q_a)\} \\ &\quad + \sigma^2\{1-\Phi(q_a)\} \frac{f_\sigma'(y)}{f_\sigma(y)} + \frac{1}{f_\sigma(y)} \lim_{n\to\infty} \mathsf S_{n,a}^{(1,2)}[f_\sigma](y). \end{align} }\]

Example 32 (Posterior absolute risk). Fix \(a\in\mathbb{R}\). Since \[|X-a| = 2(X-a)_+-(X-a),\] Example 31 gives \[\boxed{ \begin{align} \mathbb{E}[|X-a|\mid Y=y,\Sigma=\sigma^2] &= 2\sigma\phi(q_a) + (a-y)\{2\Phi(q_a)-1\} \\ &\quad + \sigma^2\{1-2\Phi(q_a)\} \frac{f_\sigma'(y)}{f_\sigma(y)} + \frac{2}{f_\sigma(y)} \lim_{n\to\infty} \mathsf S_{n,a}^{(1,2)}[f_\sigma](y). \end{align} }\]

Example 33 (Posterior pinball loss). Fix \(a\in\mathbb{R}\) and \(\tau\in(0,1)\). Let \[\rho_\tau(z) = \tau z_+ + (1-\tau)(-z)_+.\] Then \[\rho_\tau(X-a) = \tau(X-a)_+ + (1-\tau)(a-X)_+.\] Combining Examples 30 and 31 yields \[\boxed{ \begin{align} \mathbb{E}[\rho_\tau(X-a)\mid Y=y,\Sigma=\sigma^2] &= \sigma\phi(q_a) + \tau(y-a)\{1-\Phi(q_a)\} \\ &\quad + (1-\tau)(a-y)\Phi(q_a) \\ &\quad + \sigma^2\{\tau-\Phi(q_a)\} \frac{f_\sigma'(y)}{f_\sigma(y)} + \frac{1}{f_\sigma(y)} \lim_{n\to\infty} \mathsf S_{n,a}^{(1,2)}[f_\sigma](y). \end{align} }\]

References↩︎

[1]
H. Robbins, “An empirical bayes approach to statistics,” in Proceedings of the Third Berkeley Symposium on Mathematical Statistics and Probability, 1954-1955, 1956, vol. I.
[2]
B. Efron, “Two modeling strategies for empirical bayes estimation,” Statistical science: a review journal of the Institute of Mathematical Statistics, vol. 29, no. 2, p. 285, 2014.
[3]
B. Efron, “Bayes, oracle bayes and empirical bayes,” Statistical science, vol. 34, no. 2, pp. 177–201, 2019.
[4]
W. James and C. Stein, “Estimation with quadratic loss,” in Proceedings of the fourth berkeley symposium on mathematical statistics and probability, 1961, vol. 1, pp. 361–379.
[5]
B. Efron, “Empirical bayes deconvolution estimates,” Biometrika, vol. 103, no. 1, pp. 1–20, 2016.
[6]
J. van Houwelingen and T. Stijnen, “Monotone empirical bayes estimators for the continuous one-parameter exponential family,” Statistica Neerlandica, vol. 37, no. 1, pp. 29–43, 1983.
[7]
C. J. Stone, “Optimal uniform rate of convergence for nonparametric estimators of a density function or its derivatives,” in Recent advances in statistics, Elsevier, 1983, pp. 393–406.
[8]
J. Pinkse and K. Schurter, “Estimates of derivatives of (log) densities and related objects,” Econometric Theory, vol. 39, no. 2, pp. 321–356, 2023.
[9]
J. Fan, “On the optimal rates of convergence for nonparametric deconvolution problems,” The Annals of Statistics, pp. 1257–1272, 1991.
[10]
B. V. Es and H. Uh, “Asymptotic normality of kernel-type deconvolution estimators,” Scandinavian Journal of Statistics, vol. 32, no. 3, pp. 467–483, 2005.
[11]
I. Dattner, A. Goldenshluger, and A. Juditsky, “On deconvolution of distribution functions,” The Annals of Statistics, pp. 2477–2501, 2011.
[12]
E. Greenshtein and T. Itskov, “Application of non-parametric empirical bayes to treatment of non-response,” Statistica Sinica, vol. 28, no. 4, pp. 2189–2208, 2018.
[13]
J. Brennan, R. K. Vinayak, and K. Jamieson, “Estimating the number and effect sizes of non-null hypotheses,” in International conference on machine learning, 2020, pp. 1123–1133.
[14]
M. Stephens, “False discovery rates: A new deal,” Biostatistics, vol. 18, no. 2, pp. 275–294, 2017.
[15]
M. J. Wainwright, High-dimensional statistics: A non-asymptotic viewpoint, vol. 48. Cambridge university press, 2019.
[16]
L. Schwartz, Théorie des distributions. Hermann, 1966.
[17]
H. Bateman, Tables of integral transforms. McGraw-Hill Book Company, 1954.
[18]
D. W. Kammler, A first course in fourier analysis. Cambridge University Press, 2007.
[19]
C. Walters, “Empirical bayes methods in labor economics,” in Handbook of labor economics, vol. 5, Elsevier, 2024, pp. 183–260.
[20]
M. Raphan and E. P. Simoncelli, “Least squares estimation without priors or supervision,” Neural computation, vol. 23, no. 2, pp. 374–420, 2011.
[21]
F. Calmon, E. Du, C. Dwork, B. Finley, and G. Franguridi, “Debiasing functions of private statistics in postprocessing,” arXiv preprint arXiv:2502.13314, 2025.
[22]
B. Efron, “Tweedie’s formula and selection bias,” Journal of the American Statistical Association, vol. 106, no. 496, pp. 1602–1614, 2011.
[23]
C. Stein, “Estimation of the mean of a multivariate normal distribution,” The Annals of Statistics, pp. 1135–1151, 1981.
[24]
F. Dyson, “A method for correcting series of parallax observations,” Monthly Notices of the Royal Astronomical Society, Vol. 86, p. 686, vol. 86, p. 686, 1926.
[25]
M. West, “Aspects of recursive bayesian estimation,” PhD thesis, University of Nottingham, 1982.
[26]
L. Pericchi and A. Smith, “Exact and approximate posterior moments for a normal location parameter,” Journal of the Royal Statistical Society Series B: Statistical Methodology, vol. 54, no. 3, pp. 793–804, 1992.
[27]
L. Pericchi, B. Sansó, and A. Smith, “Posterior cumulant relationships in bayesian inference involving the exponential family,” Journal of the American Statistical Association, vol. 88, no. 424, pp. 1419–1426, 1993.
[28]
N. G. Polson, “A representation of the posterior mean for a location model,” Biometrika, vol. 78, no. 2, pp. 426–430, 1991, Accessed: Nov. 21, 2025. [Online].
[29]
N. G. Polson and L. Sun, “Bayesian l 0-regularized least squares,” Applied Stochastic Models in Business and Industry, vol. 35, no. 3, pp. 717–731, 2019.
[30]
H. Robbins, “Estimating many variances,” in Statistical decision theory and related topics III, Elsevier, 1982, pp. 251–261.
[31]
J. Shi and W. Song, “Nonlinear statistics inferences with Laplace measurement error,” J. Sys. Sci & Math. Scis, vol. 35, no. 12, pp. 1510–1528, 2015.
[32]
Q. Hillebrand, V. Suppakitpaisarn, and T. Shibuya, “Unbiased locally private estimator for polynomials of laplacian variables,” in Proceedings of the 29th ACM SIGKDD conference on knowledge discovery and data mining, 2023, pp. 741–751.
[33]
B. Efron, Large-scale inference: Empirical bayes methods for estimation, testing, and prediction, vol. 1. Cambridge University Press, 2012.
[34]
W. Tang, N. Touzi, Z. Zhang, and X. Y. Zhou, “Tweedie’s formulae and diffusion generative models beyond gaussian,” arXiv preprint arXiv:2605.19391, 2026.
[35]
A. Montanari, “Sampling, diffusions, and stochastic localization,” arXiv preprint arXiv:2305.10690, 2023.
[36]
Y. Song, J. Sohl-Dickstein, D. P. Kingma, A. Kumar, S. Ermon, and B. Poole, “Score-based generative modeling through stochastic differential equations,” arXiv preprint arXiv:2011.13456, 2020.
[37]
J. Sohl-Dickstein, E. Weiss, N. Maheswaranathan, and S. Ganguli, “Deep unsupervised learning using nonequilibrium thermodynamics,” in International conference on machine learning, 2015, pp. 2256–2265.
[38]
H. Hong and E. Tamer, “A simple estimator for nonlinear error in variable models,” Journal of Econometrics, vol. 117, no. 1, pp. 1–19, 2003.
[39]
J. Shi, J. Feng, and W. Song, “Estimation in linear regression with Laplace measurement error using Tweedie-type formula,” Journal of Systems Science and Complexity, vol. 32, no. 4, pp. 1211–1230, 2019.
[40]
L. Liu, H. R. Moon, and F. Schorfheide, “Forecasting with dynamic panel data models,” Econometrica, vol. 88, no. 1, pp. 171–201, 2020, doi: https://doi.org/10.3982/ECTA14952.
[41]
T. Liang, “Distributional shrinkage I: Universal denoisers in multi-dimensions,” arXiv preprint arXiv:2511.09500, 2025.
[42]
T. Liang, “Distributional shrinkage II: Optimal transport denoisers with higher-order scores,” arXiv preprint arXiv:2512.09295, 2025.
[43]
C. Butucea and F. Comte, Adaptive estimation of linear functionals in the convolution model and applications,” Bernoulli, vol. 15, no. 1, pp. 69–98, 2009, doi: 10.3150/08-BEJ146.
[44]
M. Pensky, “Minimax theory of estimation of linear functionals of the deconvolution density with or without sparsity,” The Annals of Statistics, vol. 45, no. 4, pp. 1516–1541, 2017.
[45]
P. Hall and A. Meister, “A ridge-parameter approach to deconvolution,” Annals of Statistics, vol. 35, pp. 1535–1558, 2007.
[46]
R. J. Carroll, D. Ruppert, L. A. Stefanski, and C. M. Crainiceanu, Measurement error in nonlinear models: A modern perspective. Chapman; Hall/CRC, 2006.
[47]
A. Meister, eBook ISBN 978-3-540-87557-4Deconvolution problems in nonparametric statistics. Berlin, Heidelberg: Springer, 2009, pp. vi, 210.
[48]
S. M. Schennach, “Estimation of nonlinear models with measurement error,” Econometrica, vol. 72, no. 1, pp. 33–75, 2004.
[49]
S. M. Schennach, “Nonparametric regression in the presence of measurement error,” Econometric Theory, vol. 20, no. 6, pp. 1046–1093, 2004.
[50]
S. M. Schennach, “Measurement error in nonlinear models – a review,” in Advances in Economics and Econometrics: Tenth World Congress, Cambridge University Press, 2013, pp. 296–337.
[51]
S. M. Schennach, “Convolution without independence,” Journal of econometrics, vol. 211, no. 1, pp. 308–318, 2019.
[52]
B. Mityagin, “The zero set of a real analytic function,” Mathematical Notes, vol. 107, no. 3, pp. 529–530, 2020.
[53]
F. Treves, Topological vector spaces, distributions and kernels. Dover Publications, 2006.
[54]
W. Rudin, Real and complex analysis, 3rd ed. New York: McGraw-Hill, 1987.
[55]
F. G. Mehler, Über die entwicklung einer funktion von beliebig vielen variablen nach Laplace’schen funktionen höherer ordnung,” Journal für die reine und angewandte Mathematik, vol. 66, pp. 161–176, 1866, doi: 10.1515/crll.1866.66.161.
[56]
L. Grafakos et al., Classical Fourier analysis, vol. 2. Springer, 2008.
[57]
A. N. Kolmogorov, “Unbiased estimates,” Izvestiya Rossiiskoi Akademii Nauk. Seriya Matematicheskaya, vol. 14, no. 4, pp. 303–326, 1950.
[58]
L. A. Stefanski, “Unbiased estimation of a nonlinear function a normal mean with application to measurement error models,” Communications in Statistics-Theory and Methods, vol. 18, no. 12, pp. 4335–4358, 1989.
[59]
V. G. Voinov and M. S. Nikulin, Unbiased estimators and their applications: Volume 1: Univariate case, vol. 263. Springer Science & Business Media, 2012.
[60]
C. Dwork and A. Roth, “The algorithmic foundations of differential privacy,” Foundations and trends® in theoretical computer science, vol. 9, no. 3–4, pp. 211–487, 2014.
[61]
L. Einav, A. Finkelstein, and N. Mahoney, “Producing health: Measuring value added of nursing homes,” Econometrica, vol. 93, no. 4, pp. 1225–1264, 2025.
[62]
R. Chetty and N. Hendren, “The impacts of neighborhoods on intergenerational mobility i: Childhood exposure effects,” The quarterly journal of economics, vol. 133, no. 3, pp. 1107–1162, 2018.
[63]
P. Kline, E. K. Rose, and C. R. Walters, “Systemic discrimination among large US employers,” The Quarterly Journal of Economics, vol. 137, no. 4, pp. 1963–2036, 2022, doi: 10.1093/qje/qjac024.
[64]
S. Moon, “Optimal policy choices under uncertainty,” arXiv preprint arXiv:2503.03910, 2025.
[65]
A. Abadie et al., “Estimating the value of evidence-based decision making.” 2026, [Online]. Available: https://arxiv.org/abs/2306.13681.
[66]
G. Chamberlain, Panel data,” in Handbook of econometrics, vol. 2, Elsevier, 1984, pp. 1247–1318.
[67]
W. Jiang and C.-H. Zhang, “Empirical bayes in-season prediction of baseball batting averages,” in Borrowing strength: Theory powering applications–a festschrift for lawrence d. brown, vol. 6, Institute of Mathematical Statistics, 2010, pp. 263–274.
[68]
A. Weinstein, Z. Ma, L. D. Brown, and C.-H. Zhang, “Group-linear empirical bayes estimates for a heteroscedastic normal mean,” Journal of the American Statistical Association, vol. 113, no. 522, pp. 698–710, 2018, doi: 10.1080/01621459.2017.1280406.
[69]
N. Ignatiadis and S. Wager, “Covariate-powered empirical bayes estimation,” Advances in Neural Information Processing Systems, vol. 32, 2019.
[70]
P. M. Kline, E. K. Rose, and C. R. Walters, “A discrimination report card,” National Bureau of Economic Research, 2024.
[71]
J. Chen, “Empirical bayes when estimation precision predicts parameters,” Econometrica, vol. 94, no. 2, pp. 305–340, 2026, doi: https://doi.org/10.3982/ECTA22935.
[72]
G. B. Folland, Real analysis: Modern techniques and their applications. John Wiley & Sons, 1999.
[73]
[74]
E. M. Stein and R. Shakarchi, “Fourier analysis. An introduction. Princeton lectures in analysis, 1,” Princeton, NJ: Princeton Univ. Press. MR1970295, vol. 44, p. 45, 2003.
[75]
I. S. Gradshteyn and I. M. Ryzhik, Table of integrals, series, and products, Eighth. Amsterdam, Netherlands: Academic Press, 2014.
[76]
M. Abramowitz and I. A. Stegun, Eds., Handbook of mathematical functions with formulas, graphs, and mathematical tables, Ninth Dover printing, tenth GPO printing. New York: Dover, 1972.
[77]
M. E. H. Ismail, Reprinted corrected paperback editionClassical and quantum orthogonal polynomials in one variable, vol. 98. Cambridge: Cambridge University Press, 2009.
[78]
W. Rudin, Principles of mathematical analysis, 3rd ed. New York: McGraw-Hill, 1976.

  1. Department of Economics, Massachusetts Institute of Technology. ↩︎

  2. The author thanks Alberto Abadie, Isaiah Andrews, Victor Chernozhukov, Anna Mikusheva, and Whitney Newey for guidance and comments.↩︎

  3. In empirical Bayes terminology, the former approach is \(g\)-modeling and the latter is \(f\)-modeling [2], [3].↩︎

  4. This shrinkage view includes the James–Stein estimator [4] as an instance: in the Gaussian sequence model with a Gaussian latent distribution, the empirical Bayes plug-in version of Tweedie’s formula yields James–Stein shrinkage up to degrees-of-freedom corrections [5].↩︎

  5. I use the term “posterior” rather than “conditional” following a Bayesian or empirical Bayes interpretation: \(X\) is the latent signal, \(Y\) is the observation, and \(\mathbb{E}[g(X)\mid Y=y]\) is the posterior expectation of \(g(X)\) after observing \(Y=y\).↩︎

  6. [19] provides a review of common applications of this model in economics.↩︎

  7. [51] emphasizes that such factorization can hold even without independence of \(X\) and \(V\). In this paper, however, full independence is needed to connect deconvolution to conditional expectations. It is also the standard assumption in additive-noise applications.↩︎

  8. A simple sufficient condition is the existence of an exponential moment: \(\mathbb{E} \left[\exp(r\|V\|_2)\right]<\infty\) for some \(r>0\). Then \(\varphi_V\) extends holomorphically to a complex neighborhood of \(\mathbb{R}^d\). Since \(\mathfrak{Re}(\varphi_V)(0)=1\), its real part is a nonzero real-analytic function. Accordingly, the zero set of \(\mathfrak{Re}(\varphi_V)\) has Lebesgue measure zero, and so does the zero set of \(\varphi_V\) [52].↩︎

  9. That is, a complete metrizable locally convex vector space. For a textbook construction of the topology, see [53], Chapter 10, Example IV.↩︎

  10. Lemma 2 gives a general sufficient condition on \(Q\) such that it defines a tempered distribution.↩︎

  11. See for instance the Cauchy posterior mean example in Appendix 1.0.1.5.2.↩︎

  12. Details of this calculation are given in Lemma 6.↩︎

  13. Examples include value-added modeling [61], the evaluation of place-based policies [62], the measurement of discrimination [63], policy targeting [64], and research production [65].↩︎

  14. Conditional statements are understood after fixing a version of \(P_{X\mid\Sigma}\). Since regular conditional laws are unique up to null sets, the conclusions are unaffected by this choice outside a \(P_\Sigma\)-null set.↩︎