`Empirikos.CressieSeheult`

— Module`CressieSeheult`

A household survey involved the participants in completing answers on question forms which were then collected and put into batches for coding. A quality control programme was implemented to check on coding accuracy for one question. The table shows the numbers of errors after sampling 42 coded questionnaires from each of 91 batches

This dataset is from the following reference:

```
> Cressie, Noel, and Allan Seheult. "Empirical Bayes estimation in sampling inspection."
Biometrika 72, no. 2 (1985): 451-458.
```

`Empirikos.AshPriors`

— Constant`AshPriors`

Empirical Bayes priors that are used in the simulations of:

Stephens, M., 2017. False discovery rates: a new deal. Biostatistics, 18(2), pp.275-294.

`Empirikos.CochranePriors`

— Constant`CochranePriors`

`Empirikos.EfronPriors`

— Constant`EfronPriors`

Empirical Bayes priors that are used in the simulations of:

Efron, B., 2016. Empirical Bayes deconvolution estimates. Biometrika, 103(1), pp.1-20.

`Empirikos.IWPriors`

— Constant`IWPriors`

Empirical Bayes priors that are used in the simulations of:

Ignatiadis, N. and Wager, S., 2019. Bias-aware confidence intervals for empirical Bayes analysis. arXiv preprint arXiv:1902.02774.

`Empirikos.MarronWandGaussianMixtures`

— Constant`MarronWandGaussianMixtures`

Flexible Gaussian Mixture distributions described in

Marron, J. Steve, and Matt P. Wand. Exact mean integrated squared error.

The Annals of Statistics (1992): 712-736.

`Empirikos.OSCPriors`

— ConstantOSCPriors

`Empirikos.AMARI`

— Type```
AMARI(convexclass::Empirikos.ConvexPriorClass,
flocalization::Empirikos.FLocalization,
solver,
plugin_G = KolmogorovSmirnovMinimumDistance(convexclass, solver))
```

Affine Minimax Anderson-Rubin intervals for empirical Bayes estimands. Here `flocalization`

is a pilot `Empirikos.FLocalization`

, `convexclass`

is a `Empirikos.ConvexPriorClass`

, `solver`

is a JuMP.jl compatible solver. `plugin_G`

is a `Empirikos.EBayesMethod`

used as an initial estimate of the marginal distribution of the i.i.d. samples $Z$.

**References**

@ignatiadis2022confidence

`Empirikos.BinomialSample`

— Type`BinomialSample(Z, n)`

An observed sample $Z$ drawn from a Binomial distribution with `n`

trials.

\[Z \sim \text{Binomial}(n, p)\]

$p$ is assumed unknown. The type above is used when the sample $Z$ is to be used for estimation or inference of $p$.

```
julia> BinomialSample(2, 10) # 2 out of 10 trials successful
ℬ𝒾𝓃(2; p, n=10)
```

`Empirikos.ChiSquaredFLocalization`

— Type`ChiSquaredFLocalization(α) <: FLocalization`

The $\chi^2$ F-localization at confidence level $1-\alpha$ for a discrete random variable taking values in $\{0,\dotsc, N\}$. It is equal to:

\[f: \sum_{x=0}^N \frac{(n \hat{f}_n(x) - n f(x))^2}{n f(x)} \leq \chi^2_{N,1-\alpha},\]

where $\chi^2_{N,1-\alpha}$ is the $1-\alpha$ quantile of the Chi-squared distribution with $N$ degrees of freedom, $n$ is the sample size, $\hat{f}_n(x)$ is the proportion of samples equal to $x$ and $f(x)$ is then population pmf.

`Empirikos.ConvexPriorClass`

— TypeAbstract type representing convex classes of probability distributions $\mathcal{G}$.

`Empirikos.DeLaValleePoussinKernel`

— Type`DeLaValleePoussinKernel(h) <: InfiniteOrderKernel`

Implements the `DeLaValleePoussinKernel`

with bandwidth `h`

to be used for kernel density estimation through the `KernelDensity.jl`

package. The De La Vallée-Poussin kernel is defined as follows:

\[K_V(x) = \frac{\cos(x)-\cos(2x)}{\pi x^2}\]

Its use case is similar to the `SincKernel`

, however it has the advantage of being integrable (in the Lebesgue sense) and having bounded total variation. Its Fourier transform is the following:

\[K^*_V(t) = \begin{cases} 1, & \text{ if } |t|\leq 1 \\ 0, &\text{ if } |t| \geq 2 \\ 2-|t|,& \text{ if } |t| \in [1,2] \end{cases}\]

`Empirikos.DeltaTuner`

— Type`DeltaTuner`

Abstract type used to represent ways of picking $\delta$ at which to solve the modulus problem, cf. Manuscript. Different choices of $\delta$ correspond to different choices of the Bias-Variance tradeoff with every choice leading to Pareto-optimal tradeoff.

`Empirikos.DiscretePriorClass`

— Type`DiscretePriorClass(support) <: Empirikos.ConvexPriorClass`

Type representing the family of all discrete distributions supported on a subset of `support`

, i.e., it represents all `DiscreteNonParametric`

distributions with `support = support`

and `probs`

taking values on the probability simplex.

Note that `DiscretePriorClass(support)(probs) == DiscreteNonParametric(support, probs)`

.

**Examples**

```
julia> gcal = DiscretePriorClass([0,0.5,1.0])
DiscretePriorClass | support = [0.0, 0.5, 1.0]
julia> gcal([0.2,0.2,0.6])
DiscreteNonParametric{Float64, Float64, Vector{Float64}, Vector{Float64}}(support=[0.0, 0.5, 1.0], p=[0.2, 0.2, 0.6])
```

`Empirikos.DvoretzkyKieferWolfowitz`

— Type`DvoretzkyKieferWolfowitz(;α = 0.05, max_constraints = 1000) <: FLocalization`

The Dvoretzky-Kiefer-Wolfowitz band (based on the Kolmogorov-Smirnov distance) at confidence level `1-α`

that bounds the distance of the true distribution function to the ECDF $\widehat{F}_n$ based on $n$ samples. The constant of the band is the sharp constant derived by Massart:

\[F \text{ distribution}: \sup_{t \in \mathbb R}\lvert F(t) - \widehat{F}_n(t) \rvert \leq \sqrt{\log(2/\alpha)/(2n)}\]

The supremum above is enforced discretely on at most `max_constraints`

number of points.

`Empirikos.EBayesMethod`

— TypeAbstract type representing empirical Bayes estimation methods.

`Empirikos.EBayesSample`

— Type`EBayesSample{T}`

Abstract type representing empirical Bayes samples with realizations of type `T`

.

`Empirikos.EBayesTarget`

— TypeAbstract type that describes Empirical Bayes estimands (which we want to estimate or conduct inference for).

`Empirikos.EmpiricalPartiallyBayesTTest`

— Type`EmpiricalPartiallyBayesTTest(; multiple_test = BenjaminiHochberg(), α = 0.05, prior = DiscretePriorClass(), solver = Hypatia.Optimizer, discretize_marginal = false, prior_grid_size = 300, lower_quantile = 0.01)`

Performs empirical partially Bayes multiple testing.

**Fields**

`multiple_test`

: Multiple testing procedure from MultipleTesting.jl (default:`BenjaminiHochberg()`

).`α`

: Significance level (default: 0.05).`prior`

: Prior distribution. Default:`DiscretePriorClass()`

. Alternatives include`Empirikos.Limma()`

or a distribution from Distributions.jl. Note: Other fields are ignored if using these alternatives.`solver`

: Optimization solver (default:`Hypatia.Optimizer`

). Not used with alternative`prior`

choices.`discretize_marginal`

: If true, discretizes marginal distribution (default: false). Not used with alternative`prior`

choices.`prior_grid_size`

: Grid size for prior distribution (default: 300). Not used with alternative`prior`

choices.`lower_quantile`

: Lower quantile for sample variances (default: 0.01).

**References**

@ignatiadis2023empirical

`Empirikos.FLocalization`

— TypeAbstract type representing F-Localizations.

`Empirikos.FLocalizationInterval`

— Type```
FLocalizationInterval(flocalization::Empirikos.FLocalization,
convexclass::Empirikos.ConvexPriorClass,
solver,
n_bisection = 100)
```

Method for computing frequentist confidence intervals for empirical Bayes estimands. Here `flocalization`

is a `Empirikos.FLocalization`

, `convexclass`

is a `Empirikos.ConvexPriorClass`

, `solver`

is a JuMP.jl compatible solver.

`n_bisection`

is relevant only for combinations of `target`

, `flocalization`

and `convexclass`

for which the Charnes-Cooper transformation is not applicable/implemented. Instead, a quasi-convex optimization problem is solved by bisection and increasing `n_bisection`

increases accuracy (at the cost of more computation).

`Empirikos.FittedFLocalization`

— TypeAbstract type representing a fitted F-Localization (i.e., wherein the F-localization has already been determined by data).

`Empirikos.FittedInfinityNormDensityBand`

— Type`FittedInfinityNormDensityBand`

The result of running `julia StatsBase.fit(opt::InfinityNormDensityBand, Zs)`

Here `opt`

is an instance of `InfinityNormDensityBand`

and `Zs`

is a vector of `AbstractNormalSample`

s distributed according to a density $f$..

**Fields:**

`a_min`

,`a_max`

,`kernel`

: These are the same as the fields in`opt::InfinityNormDensityBand`

.`C∞`

: The half-width of the L∞ band.`fitted_kde`

: The fitted`KernelDensity`

object.

`Empirikos.FlatTopKernel`

— Type`FlatTopKernel(h) < InfiniteOrderKernel`

Implements the `FlatTopKernel`

with bandwidth `h`

to be used for kernel density estimation through the `KernelDensity.jl`

package. The flat-top kernel is defined as follows:

\[K(x) = \frac{\sin^2(1.1x/2)-\sin^2(x/2)}{\pi x^2/ 20}.\]

Its use case is similar to the `SincKernel`

, however it has the advantage of being integrable (in the Lebesgue sense) and having bounded total variation. Its Fourier transform is the following:

\[K^*(t) = \begin{cases} 1, & \text{ if } t|\leq 1 \\ 0, &\text{ if } |t| \geq 1.1 \\ 11-10|t|,& \text{ if } |t| \in [1,1.1] \end{cases}\]

```
julia> Empirikos.FlatTopKernel(0.1)
FlatTopKernel | bandwidth = 0.1
```

`Empirikos.FoldedNormalSample`

— Type`FoldedNormalSample(Z,σ)`

An observed sample $Z$ equal to the absolute value of a draw from a Normal distribution with known variance $\sigma^2 > 0$.

\[Z = |Y|, Y\sim \mathcal{N}(\mu, \sigma^2)\]

$\mu$ is assumed unknown. The type above is used when the sample $Z$ is to be used for estimation or inference of $\mu$.

`Empirikos.GaussianScaleMixtureClass`

— Type`GaussianScaleMixtureClass(σs) <: Empirikos.ConvexPriorClass`

Type representing the family of mixtures of Gaussians with mean `0`

and standard deviations equal to `σs`

. `GaussianScaleMixtureClass(σs)`

represents the same class of distributions as `MixturePriorClass.(Normal.(0, σs))`

```
julia> gcal = GaussianScaleMixtureClass([1.0,2.0])
GaussianScaleMixtureClass | σs = [1.0, 2.0]
julia> gcal([0.2,0.8])
MixtureModel{Normal{Float64}}(K = 2)
components[1] (prior = 0.2000): Normal{Float64}(μ=0.0, σ=1.0)
components[2] (prior = 0.8000): Normal{Float64}(μ=0.0, σ=2.0)
```

`Empirikos.HalfCIWidth`

— Type`HalfCIWidth(n::Integer, α::Float64) <: DeltaTuner`

A `DeltaTuner`

that chooses the `δ ≧ δ_min`

the optimizes the worst-case confidence interval width. Here `n`

is the sample size used for estimation.

`Empirikos.InfinityNormDensityBand`

— Type```
InfinityNormDensityBand(;a_min,
a_max,
kernel = Empirikos.FlatTopKernel(),
bootstrap = :Multinomial,
nboot = 1000,
α = 0.05,
rng = Random.MersenneTwister(1)
) <: FLocalization
```

This struct contains hyperparameters that will be used for constructing a neighborhood of the marginal density. The steps of the method (and corresponding hyperparameter meanings) are as follows

- First a kernel density estimate $\bar{f}$ with
`kernel`

is fit to the data. - Second, a
`bootstrap`

(options:`:Multinomial`

or`Poisson`

) with`nboot`

bootstrap replicates will be used to estimate $c_n$, such that:

\[\liminf_{n \to \infty}\mathbb{P}\left[\sup_{x \in [a_{\text{min}} , a_{\text{max}}]} | \bar{f}(x) - f(x)| \leq c_ n\right] \geq 1-\alpha\]

Note that the bound is valid from `a_min`

to `a_max`

. `α`

is the nominal level and finally `rng`

sets the seed for the bootstrap samples.

`Empirikos.KolmogorovSmirnovMinimumDistance`

— Type`KolmogorovSmirnovMinimumDistance(convexclass, solver) <: Empirikos.EBayesMethod`

Given $n$ i.i.d. samples from the empirical Bayes problem with prior $G$ known to lie in the `convexclass`

$\mathcal{G}$ , estimate $G$ as follows:

\[\widehat{G}_n \in \operatorname{argmin}_{G \in \mathcal{G}}\{\sup_{t \in \mathbb R}\lvert F_G(t) - \widehat{F}_n(t)\rvert\},\]

where $\widehat{F}_n$ is the ECDF of the samples. The optimization is conducted by a JuMP compatible `solver`

.

`Empirikos.LinearEBayesTarget`

— Type`LinearEBayesTarget <: EBayesTarget`

Abstract type that describes Empirical Bayes estimands that are linear functionals of the prior `G`

.

`Empirikos.MarginalDensity`

— Type`MarginalDensity(Z::EBayesSample) <: LinearEBayesTarget`

**Example call**

`MarginalDensity(StandardNormalSample(2.0))`

**Description**

Describes the marginal density evaluated at $Z=z$ (e.g. $Z=2$ in the example above). In the example above the sample is drawn from the hierarchical model

\[\mu \sim G, Z \sim \mathcal{N}(0,1)\]

In other words, letting $\varphi$ the Standard Normal pdf

\[L(G) = \varhi \star dG(z)\]

Note that `2.0`

has to be wrapped inside `StandardNormalSample(2.0)`

since this target depends not only on `G`

and the location, but also on the likelihood.

`Empirikos.MixturePriorClass`

— Type`MixturePriorClass(components) <: Empirikos.ConvexPriorClass`

Type representing the family of all mixture distributions with mixing components equal to `components`

, i.e., it represents all `MixtureModel`

distributions with `components = components`

and `probs`

taking values on the probability simplex.

Note that `MixturePriorClass(components)(probs) == MixtureModel(components, probs)`

.

**Examples**

```
julia> gcal = MixturePriorClass([Normal(0,1), Normal(0,2)])
MixturePriorClass (K = 2)
Normal{Float64}(μ=0.0, σ=1.0)
Normal{Float64}(μ=0.0, σ=2.0)
julia> gcal([0.2,0.8])
MixtureModel{Normal{Float64}}(K = 2)
components[1] (prior = 0.2000): Normal{Float64}(μ=0.0, σ=1.0)
components[2] (prior = 0.8000): Normal{Float64}(μ=0.0, σ=2.0)
```

`Empirikos.NPMLE`

— Type`NPMLE(convexclass, solver) <: Empirikos.EBayesMethod`

Given $n$ independent samples $Z_i$ from the empirical Bayes problem with prior $G$ known to lie in the `convexclass`

$\mathcal{G}$, estimate $G$ by Nonparametric Maximum Likelihood (NPMLE)

\[\widehat{G}_n \in \operatorname{argmax}_{G \in \mathcal{G}}\left\{\sum_{i=1}^n \log( f_{i,G}(Z_i)) \right\},\]

where $f_{i,G}(z) = \int p_i(z \mid \mu) dG(\mu)$ is the marginal density of the $i$-th sample. The optimization is conducted by a JuMP compatible `solver`

.

`Empirikos.NonCentralHypergeometricSample`

— Type`NonCentralHypergeometricSample`

Empirical Bayes sample type used to represent a 2×2 contigency table drawn from Fisher's noncentral hypergeometric distribution conditionally on table margins. The goal is to conduct inference for the log odds ratio θ.

More concretely, suppose we observe the following contigency table. | | Outcome 1 | Outcome 2 | | |:–––-:|:––––-:|:––––-:|:–––-:| |Stratum 1| Z₁ | X₁ | n₁ | |Stratum 2| Z₂ | X₂ | n₂ | | | Z₁pZ₂ | . | . |

This table can be turned into an empirical Bayes sample through either of the following calls:

```
NonCentralHypergeometricSample(Z₁, n₁, n₂, Z₁pZ₂)
NonCentralHypergeometricSample(Z₁, X₁, Z₂, X₂; margin_entries=false)
```

The likelihood of the above as a function of the log odds ratio θ is given by:

\[\frac{\binom{n_1}{Z_1}\binom{n_2}{Z_2} \exp(\theta Z_1)}{\sum_{t}\binom{n_1}{t}\binom{n_2}{Z_1pZ_2 - t}\exp(\theta t)}.\]

`Empirikos.NormalChiSquareSample`

— Type`NormalChiSquareSample(Z, S², ν)`

This type represents a tuple $(Z, S^2)$ consisting of the following two measurements:

`Z`

, a Gaussian measurement $Z \sim \mathcal{N}(\mu, \sigma^2)$ centered around $\mu$ with variance $\sigma^2$,`S²`

, an independent unbiased measurement $S^2$ of $\sigma^2$ whose law is the scaled $\chi^2$ distribution with`ν`

($\nu \geq 1$) degrees of freedom:

\[(Z, S) \, \sim \, \mathcal{N}(\mu, \sigma^2) \otimes \frac{\sigma^2}{\nu} \chi^2_{\nu}.\]

Here $\sigma^2 > 0$ and $\mu \in \mathbb R$ are assumed unknown. $(Z, S^2)$ is to be used for estimation or inference of $\mu$ and $\sigma^2$.

`Empirikos.NormalSample`

— Type`NormalSample(Z,σ)`

An observed sample $Z$ drawn from a Normal distribution with known variance $\sigma^2 > 0$.

\[Z \sim \mathcal{N}(\mu, \sigma^2)\]

$\mu$ is assumed unknown. The type above is used when the sample $Z$ is to be used for estimation or inference of $\mu$.

```
julia> NormalSample(0.5, 1.0) #Z=0.5, σ=1
N(0.5; μ, σ=1.0)
```

`Empirikos.PoissonSample`

— Type`PoissonSample(Z, E)`

An observed sample $Z$ drawn from a Poisson distribution,

\[Z \sim \text{Poisson}(\mu \cdot E).\]

The multiplying intensity $E$ is assumed to be known (and equal to `1.0`

by default), while $\mu$ is assumed unknown. The type above is used when the sample $Z$ is to be used for estimation or inference of $\mu$.

```
julia> PoissonSample(3)
𝒫ℴ𝒾(3; μ)
julia> PoissonSample(3, 1.5)
𝒫ℴ𝒾(3; μ⋅1.5)
```

`Empirikos.PosteriorDensity`

— Type`PosteriorDensity(Z::EBayesSample, μ) <: AbstractPosteriorTarget`

Type representing the posterior density given Z at $\mu$, i.e.,

\[p_G(\mu \mid Z_i = z)\]

`Empirikos.PosteriorMean`

— Type`PosteriorMean(Z::EBayesSample) <: AbstractPosteriorTarget`

Type representing the posterior mean, i.e.,

\[E_G[\mu_i \mid Z_i = z]\]

`Empirikos.PosteriorProbability`

— Type`PosteriorProbability(Z::EBayesSample, s) <: AbstractPosteriorTarget`

Type representing the posterior probability, i.e.,

\[\Prob_G[\mu_i \in s \mid Z_i = z]\]

`Empirikos.PosteriorSecondMoment`

— Type`PosteriorSecondMoment(Z::EBayesSample) <: AbstractPosteriorTarget`

Type representing the second moment of the posterior centered around c, i.e.,

\[E_G[(\mu_i-c)^2 \mid Z_i = z]\]

`Empirikos.PosteriorVariance`

— Type`PosteriorVariance(Z::EBayesSample) <: AbstractPosteriorTarget`

Type representing the posterior variance, i.e.,

\[V_G[\mu_i \mid Z_i = z]\]

`Empirikos.PriorDensity`

— Type`PriorDensity(z::Float64) <: LinearEBayesTarget`

**Example call**

```
julia> PriorDensity(2.0)
PriorDensity{Float64}(2.0)
```

**Description**

This is the evaluation functional of the density of $G$ at `z`

, i.e., $L(G) = G'(z) = g(z)$ or in Julia code `L(G) = pdf(G, z)`

.

`Empirikos.RMSE`

— Type`RMSE(n::Integer) <: DeltaTuner`

A `DeltaTuner`

to optimizes the worst-case (root) mean squared error. Here `n`

is the sample size used for estimation.

`Empirikos.ScaledChiSquareSample`

— Type`ScaledChiSquareSample(Z, ν)`

An observed sample $Z$ drawn from a scaled chi-square distribution with unknown scale $\sigma^2 > 0$.

\[Z \sim \frac{\sigma^2}{\nu}}\chi^2_{\nu}\]

$\sigma^2$ is assumed unknown. The type above is used when the sample $Z$ is to be used for estimation or inference of $\mu$.

`Empirikos.SincKernel`

— Type`SincKernel(h) <: InfiniteOrderKernel`

Implements the `SincKernel`

with bandwidth `h`

to be used for kernel density estimation through the `KernelDensity.jl`

package. The sinc kernel is defined as follows:

\[K_{\text{sinc}}(x) = \frac{\sin(x)}{\pi x}\]

It is not typically used for kernel density estimation, because this kernel is not a density itself. However, it is particularly well suited to deconvolution problems and estimation of very smooth densities because its Fourier transform is the following:

\[K^*_{\text{sinc}}(t) = \mathbf 1( t \in [-1,1])\]

`Empirikos.StandardNormalSample`

— Type`StandardNormalSample(Z)`

An observed sample $Z$ drawn from a Normal distribution with known variance $\sigma^2 =1$.

\[Z \sim \mathcal{N}(\mu, 1)\]

$\mu$ is assumed unknown. The type above is used when the sample $Z$ is to be used for estimation or inference of $\mu$.

```
julia> StandardNormalSample(0.5) #Z=0.5
N(0.5; μ, σ=1.0)
```

`Empirikos.SymmetricDiscretePriorClass`

— Type`SymmetricDiscretePriorClass(support) <: Empirikos.ConvexPriorClass`

Type representing the family of all symmetric discrete distributions supported on a subset of `support`

∩`-support`

, i.e., it represents all `DiscreteNonParametric`

distributions with `support = [support;-support]`

and `probs`

taking values on the probability simplex (so that components with same magnitude, but opposite sign have the same probability). `support`

should include the nonnegative support points only.

`Empirikos.TruncatedPoissonSample`

— Type`TruncatedPoissonSample(Z, E)`

An observed sample $Z$ drawn from a truncated Poisson distribution,

\[Z \sim \text{Poisson}(\mu \cdot E) \mid Z \geq 1.\]

The multiplying intensity $E$ is assumed to be known (and equal to `1.0`

by default), while $\mu$ is assumed unknown. The type above is used when the sample $Z$ is to be used for estimation or inference of $\mu$.

```
TruncatedPoissonSample(3)
TruncatedPoissonSample(3, 1.5)
```

`Base.denominator`

— Method`Base.denominator(target::AbstractPosteriorTarget)`

Suppose a posterior target $\theta_G(z)$, such as the posterior mean can be written as:

\[\theta_G(z) = \frac{ a_G(z)}{f_G(z)} = \frac{ \int h(\mu)dG(\mu)}{\int p(z \mid \mu)dG(\mu)}.\]

For example, for the posterior mean $h(\mu) = \mu \cdot p(z \mid \mu)$. Then `Base.denominator`

returns the linear functional representing $G \mapsto f_G(z)$ (i.e., typically the marginal density). Also see `Base.numerator(::AbstractPosteriorTarget)`

.

`Base.numerator`

— Method`Base.numerator(target::AbstractPosteriorTarget)`

Suppose a posterior target $\theta_G(z)$, such as the posterior mean can be written as:

\[\theta_G(z) = \frac{ a_G(z)}{f_G(z)} = \frac{ \int h(\mu)dG(\mu)}{\int p(z \mid \mu)dG(\mu)}.\]

For example, for the posterior mean $h(\mu) = \mu \cdot p(z \mid \mu)$. Then `Base.numerator`

returns the linear functional representing $G \mapsto a_G(z)$.

`Distributions.ccdf`

— Method`ccdf(prior::Distribution, Z::EBayesSample)`

Given a `prior`

$G$ and `EBayesSample`

$Z$, evaluate the complementary CDF of the marginal distribution of $Z$ at `response(Z)`

.

`Distributions.cdf`

— Method`cdf(prior::Distribution, Z::EBayesSample)`

Given a `prior`

$G$ and `EBayesSample`

$Z$, evaluate the CDF of the marginal distribution of $Z$ at `response(Z)`

.

`Distributions.cf`

— Method`cf(::LinearEBayesTarget, t)`

The characteristic function of $L(\cdot)$, a `LinearEBayesTarget`

, which we define as follows:

For $L(\cdot)$ which may be written as $L(G) = \int \psi(\mu)dG\mu$ (for a measurable function $\psi$) this returns the Fourier transform of $\psi$ evaluated at t, i.e., $\psi^*(t) = \int \exp(it x)\psi(x)dx$. Note that $\psi^*(t)$ is such that for distributions $G$ with density $g$ (and $g^*$ the Fourier Transform of $g$) the following holds:

\[L(G) = \frac{1}{2\pi}\int g^*(\mu)\psi^*(\mu) d\mu\]

`Distributions.pdf`

— Method`pdf(prior::Distribution, Z::EBayesSample)`

Given a `prior`

$G$ and `EBayesSample`

$Z$, compute the marginal density of `Z`

.

**Examples**

```
julia> Z = StandardNormalSample(1.0)
N(1.0; μ, σ=1.0)
julia> prior = Normal(2.0, sqrt(3))
Normal{Float64}(μ=2.0, σ=1.7320508075688772)
julia> pdf(prior, Z)
0.17603266338214976
julia> pdf(Normal(2.0, 2.0), 1.0)
0.17603266338214976
```

`Empirikos.invtrigamma`

— Method`invtrigamma(x)`

Compute the inverse `trigamma`

function of `x`

.

`Empirikos.likelihood_distribution`

— Function`likelihood_distribution(Z::EBayesSample, μ::Number)`

Returns the distribution $p(\cdot \mid \mu)$ of $Z \mid \mu$ (the return type being a `Distributions.jl`

Distribution).

**Examples**

```
julia> likelihood_distribution(StandardNormalSample(1.0), 2.0)
Normal{Float64}(μ=2.0, σ=1.0)
```

`Empirikos.marginalize`

— Function`marginalize(Z::EBayesSample, prior::Distribution)`

Given a `prior`

distribution $G$ and `EBayesSample`

$Z$, return that marginal distribution of $Z$. Works for `EBayesSample{Missing}`

`, i.e., no realization is needed.

**Examples**

`jldoctest julia> marginalize(StandardNormalSample(1.0), Normal(2.0, sqrt(3))) Normal{Float64}(μ=2.0, σ=1.9999999999999998)`

`

`StatsAPI.confint`

— Method```
StatsBase.confint(method::AMARI,
target::Empirikos.EBayesTarget,
Zs;
level=0.95)
```

Form a confidence interval for the `Empirikos.EBayesTarget`

`target`

with coverage `level`

based on the samples `Zs`

using the `AMARI`

`method`

.

`StatsAPI.fit`

— Method`fit(test::EmpiricalPartiallyBayesMultipleTest, Zs::AbstractArray{<:NormalChiSquareSample})`

Fit the empirical partially Bayes multiple testing model.

**Arguments**

`test`

: An`EmpiricalPartiallyBayesMultipleTest`

object.`Zs`

: An array of`NormalChiSquareSample`

objects.

**Returns**

A named tuple containing the following fields:

`method`

: The`EmpiricalPartiallyBayesMultipleTest`

object.`prior`

: The estimated prior distribution.`pvalue`

: An array of empirical partially Bayes p-values.`cutoff`

: The cutoff value (such that all hypotheses with pvalue ≤ cutoff are rejected).`adjp`

: An array of adjusted p-values.`rj_idx`

: An array of rejection indicators.`total_rejections`

: The total number of rejections.

`StatsAPI.response`

— Method`response(Z::EBayesSample{T})`

Returns the concrete realization of `Z`

as type `T`

, thus dropping the information about the likelihood.

**Examples**

```
julia> response(StandardNormalSample(1.0))
1.0
```

`Empirikos.Neighborhoods`

— Module`Neighborhoods`

**The impact of Neighborhoods: Moving to opportunity**

The reference for this dataset is the following:

Raj Chetty and Nathaniel Hendren.

The impacts of neighborhoods on intergenerational mobility II: County-level estimates. The Quarterly Journal of Economics, 133(3):1163– 1228, 2018.

`Empirikos.Thyrion`

— Module```
Thyrion
LA ROYALE BELGE
A statistic covering vehicles in the category 'Tourism and Business' and
belonging to the 2 lower classes of the rate, observed all during an entire year,
gave the following results in which:
```

`Empirikos.CollinsLangman`

— Module`CollinsLangman`

`Empirikos.Prostate`

— Module`Prostate`

The dataset is from the following reference:

Dinesh Singh, Phillip G. Febbo, Kenneth Ross, Donald G. Jackson, Judith Manola,

Christine Ladd, Pablo Tamayo, Andrew A. Renshaw, Anthony V. D’Amico, Jerome P. Richie, Eric S. Lander, Massimo Loda, Philip W. Kantoff, Todd R. Golub, and William R. Sellers. Gene expression correlates of clinical prostate cancer behavior. Cancer cell, 1(2): 203–209, 2002.

See the following monograph for further illustrations of empirical Bayes methods on this dataset:

Bradley Efron. Large-scale inference: Empirical Bayes methods for estimation, testing,

and prediction. Cambridge University Press, 2012