Gaussian Discrimnant Analysis

Gaussian Discrimnant Analysis#

Multivariate Gaussian#

Recall the multivariate gaussian can be represented as in terms of a quadratic function quadratic function \(q(x)\) which is called the quadratic form,

\[\begin{split} \begin{gather*} P(x) = (2 \pi \det \Sigma)^{-1/2}\exp\left[-\frac{1}{2} Q(v)\right]\\ Q(x) = v^\top\Sigma^{-1} v \end{gather*} \end{split}\]

  • \(v​\) : Deviation vector \(X_i-\mu​\)

  • \(X_i​\) : A row of data

  • \(\mu\) : A vector with each entry as the mean of the feature column.

The quadratic form \(q(x)\) describes the shape of the isocontours \(q(x) = c\) (for some real scalar \(c\)). For the Gaussian, the shape is a \(\dim(v)\) ellipsoid due to the mapping of a semi-circle function to parabolic function specified by,

\[ |v| \longrightarrow \left\lvert\Sigma^{-1/2} v\right\rvert \]

Quadratic Discrimnant Analysis#

For each class in \(c : \{1,2,3,\ldots,C\}\) there exists a sample covariance matrix \(\hat\Sigma\),

\[ \hat \Sigma_c = \frac{1}{n_c}\sum_{y_i=c} (X_i - \hat \mu_c)(X_i - \hat \mu_c)^\top \]

The Bayes optimal rule maximizes \(P\) or rather \(\log P\) over the class \(c\) as its parameter. An equivalent description is to maximize the logistic function,

\[ \hat y = \mathop{\arg\max}_c \bigg[Q_c(x) - Q_d(x)\bigg] \]

Linear Discrimnant Analysis#

Every class has the same sample covariance matrix which is calculated by the mean of each class’s covariance matrix. This is called the pooled within-class covariance matrix,

\[ \hat\Sigma = \frac{1}{n}\sum_c\sum_{y_i = c} (X_i - \hat\mu_c)(X_i - \hat\mu_c)^\top \]

The Bayes optimal rule is equivalently a linear function,

\[ \hat y = \mathop{\arg\max}_c \bigg[(\mu_c-\mu_d)^\top \Sigma^{-1} x - + \log \frac{\pi_c}{\pi_d}\bigg] \]

Transformations#

  • Decorrelating: \(XU\)

  • Sphering: \(X\hat\Sigma^{-1/2}​\)

  • Whitening: Decorrelating + Sphering

Relations to Principal Component Analysis#

\[\begin{split} P(x) = (2 \pi \det \Sigma)^{-1/2}\exp\left[-\frac{1}{2} v^\top\Sigma^{-1} v\right]~; \qquad v := x-\mu\\ \end{split}\]
\[\begin{split} \begin{align*} q(v) &= v^\top \Sigma^{-1} v \\ &= \underbrace{v^\top Q}_{u^\top} \Lambda^{-1}\underbrace{Q^\top v}_u\\ &= u^\top \Lambda^{-1} u\\ &= \sum_{j=1}^{d} \lambda^{-1} u_j^2\\ &= \sum_{j=1}^{d} \frac{1}{\sigma^2} u_j^2 \end{align*} \end{split}\]
\[ \det \Sigma = \prod_{j=1}^d \lambda_j = \prod_{j=1}^d \sigma_j^2 \nonumber \]
\[\begin{split} \begin{align*} P(x) &= \left(2 \pi \prod \sigma_j^2 \right)^{-1/2}\exp\left[-\frac{1}{2} \sum_{j=1}^{d} \frac{1}{\sigma^2} u_j^2\right]\\ &= \prod_{j=1}^d (2\pi \sigma_j^2)^{-1/2}\exp\left[-\frac{u_j^2}{2\sigma^2_j}\right] \end{align*}\\ u = Q^\top(x-\mu) \end{split}\]
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