Last updated: 2018-09-05
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Building on this simple univariate regression, we define the ‘single effect (multiple) regression’ model (SER model), to be a multiple regression model in which it is assumed that exactly one of p covariates has a non-zero effect.
The SER model is \[ \begin{align*} \mathbf{y} &= X \boldsymbol{\beta} + \boldsymbol{\epsilon} \quad \boldsymbol{\epsilon}\sim N_{n}(0, \frac{1}{\tau}I) \\ \boldsymbol{\beta} &= \boldsymbol{\gamma} \beta \\ \boldsymbol{\gamma} &\sim Multinomial(1,\boldsymbol{\pi}) \\ \beta &\sim N(0, \frac{1}{\tau_{0}}) \end{align*} \] As we have shown in Bayesian Linear Regression, the posterior on the indicator vector \(\boldsymbol{\gamma}\) is: \[ \boldsymbol{\gamma}|\mathbf{y},X,\tau,\tau_{0},\boldsymbol{\pi} \sim Multinomial(1, \boldsymbol{\alpha}) \\ \alpha_{j} = \frac{\pi_{j}BF(\mathbf{y}, \mathbf{x}_{j})}{\sum_{k}\pi_{k}BF(\mathbf{y}, \mathbf{x}_{k})} \] The \(\boldsymbol{\alpha}\) is the vector of ‘Posterior Inclusion Probabilitie’.
Conditional on the jth element of \(\boldsymbol{\gamma}\) being non-zero, \[ \beta | \gamma_{j} = 1, \mathbf{y}, X, \tau, \tau_{0} \sim N(\mu_{1j}, \frac{1}{\tau_{1j}}) \\ \tau_{1j} = \tau\mathbf{x}_{j}^{T}\mathbf{x}_{j} + \tau_{0} \\ \mu_{1j} = \frac{\tau\mathbf{x}_{j}^{T}\mathbf{y}}{\tau_{1j}} \]
The variational lower bound: \[ \log p(\mathbf{y}) = L(q(\boldsymbol{\beta})) + KL\left[q(\boldsymbol{\beta} \| p(\boldsymbol{\beta}|\mathbf{y})\right] \]
Here we have the exact posterior \(p(\boldsymbol{\beta}|\mathbf{y})\). So the lower bound is same as the log likelihood.
\[ \begin{align*} p(\mathbf{y}|X, \boldsymbol{\pi}, \tau_{0}, \tau) &= \int p(\mathbf{y}, \beta, \boldsymbol{\gamma}|X, \boldsymbol{\pi}, \tau_{0}, \tau) d \boldsymbol{\gamma} d \beta \\ &= \sum_{j=1}^{p}\pi_{j}\int \left(\frac{1}{\sqrt{2\pi/\tau}}\right)^{n}\exp\left(-\frac{\tau\|\mathbf{y}-X\boldsymbol{\gamma}\beta\|^{2}}{2}\right) N(\beta; 0, 1/\tau_{0}) d \beta \\ &= \sum_{j=1}^{p}\pi_{j} N(\hat{\beta}_{j}; 0, \frac{1}{\tau\mathbf{x}_{j}^{T}\mathbf{x}_{j}} + \frac{1}{\tau_{0}}) \\ &= \sum_{j=1}^{p}\pi_{j} \frac{N(\hat{\beta}_{j}; 0, \frac{1}{\tau\mathbf{x}_{j}^{T}\mathbf{x}_{j}} + \frac{1}{\tau_{0}})}{N(\mathbf{y}; 0, \frac{1}{\tau}I) } N(\mathbf{y}; 0, \frac{1}{\tau}I) \\ &= \sum_{j=1}^{p}\pi_{j} \frac{N(\hat{\beta}_{j}; 0, \frac{1}{\tau\mathbf{x}_{j}^{T}\mathbf{x}_{j}} + \frac{1}{\tau_{0}})}{N(\hat{\beta}_{j}; 0, \frac{1}{\tau\mathbf{x}_{j}^{T}\mathbf{x}_{j}})} N(\mathbf{y}; 0, \frac{1}{\tau}I) \\ &= \sum_{j=1}^{p} \pi_{j} BF(\mathbf{y}, \mathbf{x}_{j}) N(\mathbf{y}; 0, \frac{1}{\tau}I) \end{align*} \]
\[ \log p(\mathbf{y}) = L(q(\boldsymbol{\beta})) = \log \left[\sum_{j=1}^{p} \pi_{j} BF(\mathbf{y}, \mathbf{x}_{j})\right] + \log N(\mathbf{y}; 0, \frac{1}{\tau}I) \]
sessionInfo()
R version 3.5.1 (2018-07-02)
Platform: x86_64-apple-darwin15.6.0 (64-bit)
Running under: macOS High Sierra 10.13.6
Matrix products: default
BLAS: /Library/Frameworks/R.framework/Versions/3.5/Resources/lib/libRblas.0.dylib
LAPACK: /Library/Frameworks/R.framework/Versions/3.5/Resources/lib/libRlapack.dylib
locale:
[1] en_US.UTF-8/en_US.UTF-8/en_US.UTF-8/C/en_US.UTF-8/en_US.UTF-8
attached base packages:
[1] stats graphics grDevices utils datasets methods base
loaded via a namespace (and not attached):
[1] workflowr_1.1.1 Rcpp_0.12.18 digest_0.6.15
[4] rprojroot_1.3-2 R.methodsS3_1.7.1 backports_1.1.2
[7] git2r_0.23.0 magrittr_1.5 evaluate_0.11
[10] stringi_1.2.4 whisker_0.3-2 R.oo_1.22.0
[13] R.utils_2.6.0 rmarkdown_1.10 tools_3.5.1
[16] stringr_1.3.1 yaml_2.2.0 compiler_3.5.1
[19] htmltools_0.3.6 knitr_1.20
This reproducible R Markdown analysis was created with workflowr 1.1.1