The Wishart distribution on a random positive-definite matrix \({\boldsymbol{X}}_{q\times q}\) is is denoted \({\boldsymbol{X}}\sim \textrm{Wish}({\boldsymbol{\Psi}}, \nu)\), and defined as \({\boldsymbol{X}}= ({\boldsymbol{L}}{\boldsymbol{Z}})({\boldsymbol{L}}{\boldsymbol{Z}})'\), where:
\({\boldsymbol{\Psi}}_{q\times q} = {\boldsymbol{L}}{\boldsymbol{L}}'\) is the positive-definite matrix scale parameter,
\(\nu > q\) is the shape parameter,
\({\boldsymbol{Z}}_{q\times q}\) is a random lower-triangular matrix with elements
\[ Z_{ij} \begin{cases} \overset{\;\textrm{iid}\;}{\sim}\mathcal{N}(0,1) & i < j \\ \overset{\:\textrm{ind}\:}{\sim}\chi^2_{(\nu-i+1)} & i = j \\ = 0 & i > j. \end{cases} \]
The log-density of the Wishart distribution is \[ \log p({\boldsymbol{X}}\mid {\boldsymbol{\Psi}}, \nu) = -\textstyle{\frac{1}{2}} \left[\mathrm{tr}({\boldsymbol{\Psi}}^{-1} {\boldsymbol{X}}) + (q+1-\nu)\log |{\boldsymbol{X}}| + \nu \log |{\boldsymbol{\Psi}}| + \nu q \log(2) + 2 \log \Gamma_q(\textstyle{\frac{\nu }{2}})\right], \] where \(\Gamma_n(x)\) is the multivariate Gamma function defined as \[ \Gamma_n(x) = \pi^{n(n-1)/4} \prod_{j=1}^n \Gamma\big(x + \textstyle{\frac{1}{2}} (1-j)\big). \]
The Inverse-Wishart distribution \({\boldsymbol{X}}\sim \textrm{InvWish}({\boldsymbol{\Psi}}, \nu)\) is defined as \({\boldsymbol{X}}^{-1} \sim \textrm{Wish}({\boldsymbol{\Psi}}^{-1}, \nu)\). Its log-density is given by \[ \log p({\boldsymbol{X}}\mid {\boldsymbol{\Psi}}, \nu) = -\textstyle{\frac{1}{2}} \left[\mathrm{tr}({\boldsymbol{\Psi}}{\boldsymbol{X}}^{-1}) + (\nu+q+1) \log |{\boldsymbol{X}}| - \nu \log |{\boldsymbol{\Psi}}| + \nu q \log(2) + 2 \log \Gamma_q(\textstyle{\frac{\nu }{2}})\right]. \]
If \({\boldsymbol{X}}_{q\times q} \sim \textrm{Wish}({\boldsymbol{\Psi}},\nu)\), the for a nonzero vector \({\boldsymbol{a}}\in \mathbb R^q\) we have \[ \frac{{\boldsymbol{a}}'{\boldsymbol{X}}{\boldsymbol{a}}}{{\boldsymbol{a}}'{\boldsymbol{\Psi}}{\boldsymbol{a}}} \sim \chi^2_{(\nu)}. \]
The Matrix-Normal distribution on a random matrix \({\boldsymbol{X}}_{p \times q}\) is denoted \({\boldsymbol{X}}\sim \textrm{MatNorm}({\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}_R, {\boldsymbol{\Sigma}}_C)\), and defined as \({\boldsymbol{X}}= {\boldsymbol{L}}{\boldsymbol{Z}}{\boldsymbol{U}}+ {\boldsymbol{\Lambda}}\), where:
The log-density of the Matrix-Normal distribution is \[ \log p({\boldsymbol{X}}\mid {\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}_R, {\boldsymbol{\Sigma}}_C) = -\textstyle{\frac{1}{2}} \left[\mathrm{tr}\big({\boldsymbol{\Sigma}}_C^{-1}({\boldsymbol{X}}-{\boldsymbol{\Lambda}})'{\boldsymbol{\Sigma}}_R^{-1}({\boldsymbol{X}}-{\boldsymbol{\Lambda}})\big) + \nu q \log(2\pi) + \nu \log |{\boldsymbol{\Sigma}}_C| + q \log |{\boldsymbol{\Sigma}}_R|\right]. \]
If \({\boldsymbol{X}}_{p \times q} \sim \textrm{MatNorm}({\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}_R, {\boldsymbol{\Sigma}}_C)\), then for nonzero vectors \({\boldsymbol{a}}\in \mathbb R^p\) and \({\boldsymbol{b}}\in \mathbb R^q\) we have \[ {\boldsymbol{a}}' {\boldsymbol{X}}{\boldsymbol{b}}\sim \mathcal{N}({\boldsymbol{a}}' {\boldsymbol{\Lambda}}{\boldsymbol{b}}, {\boldsymbol{a}}'{\boldsymbol{\Sigma}}_R{\boldsymbol{a}}\cdot {\boldsymbol{b}}'{\boldsymbol{\Sigma}}_C{\boldsymbol{b}}). \]
The Matrix-Normal Inverse-Wishart Distribution on a random matrix \({\boldsymbol{X}}_{p \times q}\) and random positive-definite matrix \({\boldsymbol{V}}_{q\times q}\) is denoted \(({\boldsymbol{X}},{\boldsymbol{V}}) \sim \textrm{MNIW}({\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}, {\boldsymbol{\Psi}}, \nu)\), and defined as \[ \begin{aligned} {\boldsymbol{X}}\mid {\boldsymbol{V}}& \sim \textrm{MatNorm}({\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}, {\boldsymbol{V}}) \\ {\boldsymbol{V}}& \sim \textrm{InvWish}({\boldsymbol{\Psi}}, \nu). \end{aligned} \]
The MNIX distribution is conjugate prior for the multivariable response regression model \[ {\boldsymbol{Y}}_{n \times q} \sim \textrm{MatNorm}({\boldsymbol{X}}_{n\times p} {\boldsymbol{\beta}}_{p \times q}, {\boldsymbol{V}}, {\boldsymbol{\Sigma}}). \] That is, if \(({\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}) \sim \textrm{MNIW}({\boldsymbol{\Lambda}}, {\boldsymbol{\Omega}}^{-1}, {\boldsymbol{\Psi}}, \nu)\), then \[ {\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}\mid {\boldsymbol{Y}}\sim \textrm{MNIW}(\hat {\boldsymbol{\Lambda}}, \hat {\boldsymbol{\Omega}}^{-1}, \hat {\boldsymbol{\Psi}}, \hat \nu), \] where \[ \begin{aligned} \hat {\boldsymbol{\Omega}}& = {\boldsymbol{X}}'{\boldsymbol{V}}^{-1}{\boldsymbol{X}}+ {\boldsymbol{\Omega}} & \hat {\boldsymbol{\Psi}}& = {\boldsymbol{\Psi}}+ {\boldsymbol{Y}}'{\boldsymbol{V}}^{-1}{\boldsymbol{Y}}+ {\boldsymbol{\Lambda}}'{\boldsymbol{\Omega}}{\boldsymbol{\Lambda}}- \hat {\boldsymbol{\Lambda}}'\hat {\boldsymbol{\Omega}}\hat {\boldsymbol{\Lambda}} \\ \hat {\boldsymbol{\Lambda}}& = \hat {\boldsymbol{\Omega}}^{-1}({\boldsymbol{X}}'{\boldsymbol{V}}^{-1}{\boldsymbol{Y}}+ {\boldsymbol{\Omega}}{\boldsymbol{\Lambda}}) & \hat \nu & = \nu + n. \end{aligned} \]
The Matrix-\(t\) distribution on a random matrix \({\boldsymbol{X}}_{p \times q}\) is denoted \({\boldsymbol{X}}\sim \textrm{MatT}({\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}_R, {\boldsymbol{\Sigma}}_C, \nu)\), and defined as the marginal distribution of \({\boldsymbol{X}}\) for \(({\boldsymbol{X}}, {\boldsymbol{V}}) \sim \textrm{MNIW}({\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}_R, {\boldsymbol{\Sigma}}_C, \nu)\). Its log-density is given by \[ \begin{aligned} \log p({\boldsymbol{X}}\mid {\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}_R, {\boldsymbol{\Sigma}}_C, \nu) & = -\textstyle{\frac{1}{2}} \Big[(\nu+p+q-1)\log | I + {\boldsymbol{\Sigma}}_R^{-1}({\boldsymbol{X}}-{\boldsymbol{\Lambda}}){\boldsymbol{\Sigma}}_C^{-1}({\boldsymbol{X}}-{\boldsymbol{\Lambda}})'| \\ & \phantom{= -\textstyle{\frac{1}{2}} \Big[} + q \log |{\boldsymbol{\Sigma}}_R| + p \log |{\boldsymbol{\Sigma}}_C| \\ & \phantom{= -\textstyle{\frac{1}{2}} \Big[} + pq \log(\pi) - \log \Gamma_q(\textstyle{\frac{\nu+p+q-1}{2}}) + \log \Gamma_q(\textstyle{\frac{\nu+q-1}{2}})\Big]. \end{aligned} \]
If \({\boldsymbol{X}}_{p\times q} \sim \textrm{MatT}({\boldsymbol{\Lambda}}, {\boldsymbol{\Sigma}}_R, {\boldsymbol{\Sigma}}_C, \nu)\), then for nonzero vectors \({\boldsymbol{a}}\in \mathbb R^p\) and \({\boldsymbol{b}}\in \mathbb R^q\) we have \[ \frac{{\boldsymbol{a}}'{\boldsymbol{X}}{\boldsymbol{b}}- \mu}{\sigma} \sim t_{(\nu -q + 1)}, \] where \[ \mu = {\boldsymbol{a}}'{\boldsymbol{\Lambda}}{\boldsymbol{b}}, \qquad \sigma^2 = \frac{{\boldsymbol{a}}'{\boldsymbol{\Sigma}}_R{\boldsymbol{a}}\cdot {\boldsymbol{b}}'{\boldsymbol{\Sigma}}_C{\boldsymbol{b}}}{\nu - q + 1}. \]
Consider the multivariate normal distribution on \(q\)-dimensional vectors \({\boldsymbol{x}}\) and \({\boldsymbol{\mu}}\) given by \[ \begin{aligned} {\boldsymbol{x}}\mid {\boldsymbol{\mu}}& \sim \mathcal{N}({\boldsymbol{\mu}}, {\boldsymbol{V}}) \\ {\boldsymbol{\mu}}& \sim \mathcal{N}({\boldsymbol{\lambda}}, {\boldsymbol{\Sigma}}). \end{aligned} \] The random-effects normal distribution is defined as the posterior distribution \({\boldsymbol{\mu}}\sim p({\boldsymbol{\mu}}\mid {\boldsymbol{x}})\), which is given by \[ {\boldsymbol{\mu}}\mid {\boldsymbol{x}}\sim \mathcal{N}\big({\boldsymbol{G}}({\boldsymbol{x}}-{\boldsymbol{\lambda}}) + {\boldsymbol{\lambda}}, {\boldsymbol{G}}{\boldsymbol{V}}\big), \qquad {\boldsymbol{G}}= {\boldsymbol{\Sigma}}({\boldsymbol{V}}+ {\boldsymbol{\Sigma}})^{-1}. \] The notation for this distribution is \({\boldsymbol{\mu}}\sim \textrm{RxNorm}({\boldsymbol{x}}, {\boldsymbol{V}}, {\boldsymbol{\lambda}}, {\boldsymbol{\Sigma}})\).
The hierarchical Normal-Normal model is defined as \[ \begin{aligned} {\boldsymbol{y}}_i \mid {\boldsymbol{\mu}}_i, {\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}& \overset{\:\textrm{ind}\:}{\sim}\mathcal{N}({\boldsymbol{\mu}}_i, {\boldsymbol{V}}_i) \\ {\boldsymbol{\mu}}_i \mid {\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}& \overset{\;\textrm{iid}\;}{\sim}\mathcal{N}({\boldsymbol{x}}_i'{\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}) \\ ({\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}) & \sim \textrm{MNIW}({\boldsymbol{\Lambda}}, \Omega^{-1}, {\boldsymbol{\Psi}}, \nu), \end{aligned} \] where:
Let \({\boldsymbol{Y}}_{n\times q} = (\boldsymbol{y}_{1},\ldots,\boldsymbol{y}_{n})\), \({\boldsymbol{X}}_{n\times p} = (\boldsymbol{x}_{1},\ldots,\boldsymbol{x}_{n})\), and \({\boldsymbol{\Theta}}_{n \times q} = (\boldsymbol{\mu}_{1},\ldots,\boldsymbol{\mu}_{n})\). If interest lies in the posterior distribution \(p({\boldsymbol{\Theta}}, {\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}\mid {\boldsymbol{Y}}, {\boldsymbol{X}})\), then a Gibbs sampler can be used to cycle through the following conditional distributions: \[ \begin{aligned} {\boldsymbol{\mu}}_i \mid {\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}, {\boldsymbol{Y}}, {\boldsymbol{X}}& \overset{\:\textrm{ind}\:}{\sim}\textrm{RxNorm}({\boldsymbol{y}}_i, {\boldsymbol{V}}_i, {\boldsymbol{x}}_i'{\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}) \\ {\boldsymbol{\beta}}, {\boldsymbol{\Sigma}}\mid {\boldsymbol{\Theta}}, {\boldsymbol{Y}}, {\boldsymbol{X}}& \sim \textrm{MNIW}(\hat {\boldsymbol{\Lambda}}, \hat {\boldsymbol{\Omega}}^{-1}, \hat {\boldsymbol{\Psi}}, \hat \nu), \end{aligned} \] where \(\hat {\boldsymbol{\Lambda}}\), \(\hat {\boldsymbol{\Omega}}\), \(\hat {\boldsymbol{\Psi}}\), and \(\hat \nu\) are obtained from the MNIW conjugate posterior formula with \({\boldsymbol{Y}}\gets {\boldsymbol{\Theta}}\).