# TTIC 31020 : Problem Set 1_1

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Maria Hyun

Last Updated

för 9 år sedan

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Creative Commons CC BY 4.0

Sammanfattning

TTIC 31020 : Problem Set 1

Författare

Maria Hyun

Last Updated

för 9 år sedan

Licens

Creative Commons CC BY 4.0

Sammanfattning

TTIC 31020 : Problem Set 1

```
\documentclass[a4paper]{article}
\usepackage[english]{babel}
\usepackage[utf8x]{inputenc}
\usepackage{amsmath}
\usepackage{amssymb}
\usepackage{graphicx}
\usepackage[colorinlistoftodos]{todonotes}
\usepackage[margin=1in]{geometry}
\title{TTIC 31020 : Problem Set 1}
\author{Maria Hyun}
\begin{document}
\maketitle
\section*{Problem1}
Show that for any $a\in\mathbb{R}^{d+1}$
\begin{center}
$E_{p(x, y)}[(y-w^{*T}x)a^Tx]=0$
\end{center}
$w^*=\arg\min\limits_{w}\sum\limits^N_{i=1}(y_i-w^Tx_i)^2\Rightarrow L(w, X, y)=L(w) = \frac{1}{N}\sum\limits_{i=1}^N(y_y-w^Tx_i)^2$
Since $w^*$ is optimal solution
\[ \frac{\partial L(w, X, y)}{\partial w}
= 0 \]Derivatices w.r.t $w_0, w_1, ..., w_d$ must all be zero
$L(w)=\frac{1}{N}\sum\limits_{i=1}^{N}(y_i-w^Tx_i)^2$
\[ \frac{\partial}{\partial w_0}L(w)=\frac{1}{N}\sum\limits_{i=0}^{N}\frac{\partial}{\partial w_0}(y_i-w^Tx_i) = 0 \]
It apply that
$\sum\limits_{i=0}^{N}(y_i-w^Tx_i) = 0$
$E_{p(x, y)}[(y-w^{*T}x)a^Tx]=\int\int((y-w^{*T}x)a^Tx)\,p(y|x)p(x)dydx=\int{E_{y|x}[y_i-w^Tx_i]}(a^Tx)p(x)dx=0$
\pagebreak
\section*{Problem2}
Explain how the original statement, regarding zero correlation between prediction errors made by $\hat{w}$ estimated by least squares with any linear function of the training ${x_i}$, follows from $E_{p(x, y)}[(y-w^{*T}x)a^Tx]=0$
\\
\\
Naturally, any model is highly optimized for the data it was trained on. The expected error the model exhibits on new data will always be higher than that it exhibits on the training data. As example, we could go out and sample 100 people and create a regression model to predict an individual's happiness based on their wealth. We can record the squared error for how well our model does on this training set of a hundred people. If we then sampled a different 100 people from the population and applied our model to this new group of people, the squared error will almost always be higher in this second case.
It is helpful to illustrate this fact with an equation. We can develop a relationship between how well a model predicts on new data (its true prediction error and the thing we really care about) and how well it predicts on the training data (which is what many modelers in fact measure).
True Prediction Error=Training Error+Training Optimism
Here, Training Optimism is basically a measure of how much worse our model does on new data compared to the training data. The more optimistic we are, the better our training error will be compared to what the true error is and the worse our training error will be as an approximation of the true error.
Training error almost always UNDER estimates test error, sometimes dramatically.
Training error usually UNDER estimates test error when the model is very complex (compared to the training set size), and is a pretty good estimate when the model is not very complex.
However, it's always possible we just get too few hard-to-predict points in the test set, or too many in the training set. Then the test error can be LESS than training error, when by chance the test set has easier cases than the training set.
\pagebreak
\section*{Problem3}
Let $\hat{w}$ be the least square estimate of the regression parameter from the unscaled $X$, and let $\hat{\tilde{w}}$ be the solution obtained from the scaled $X$. Show that the scaling does not change optimality, in the sense that $\hat{w}^{T}x=\hat{\tilde{w}}^{T}\tilde{x}$.
First, note that scaling can be represented as a linear operation $C$ composed of the scaling factors along its main diagonal.
\[C=
\begin{bmatrix}
1 & & & \\
& c_{1} & & \\
& & \ddots & \\
& & & c_{d}
\end{bmatrix}
\]
Using the scaling Operator $C$, we can express the scaled inputs $\tilde{x}$ and design matrix $\tilde{X}$ as function of $x$ and $X$ respectively.
\begin{center}
\begin{equation}
\tilde{x} = Cx \quad\quad \tilde{X}=XC
\end{equation}
\end{center}
As was demonstrated in class, under the Gaussian noise model, the ML estimate of the regression parameters in given by
\begin{center}
$\hat{x} = (X^{T}X)^{-1}X^{T}y$
\end{center}
Using the expression in Equation 5, we find
\begin{center}
$\hat{\tilde{w}} = (\tilde{X}^{T}\tilde{X})^{-1}\tilde{X}^Ty = ((XC)^{T}XC)^{-1}(XC)^{T}y=(C^{X}X^{T}XC)^{-1}C^{T}X^{T}y$
\end{center}
At this point, we can apply the following matrix identity: if the individual inverses $A^{-1}$ and $B^{-1}$ exits, then $(AB)^{-1} = B^{-1}A^{-1}$. Since $C$ is real, symmetric square matrix, $C^{-1}$ must exist. Similarly, $X^{T}X$ is real, symmetric square matrix so $(X^{T}XC)^{-1}$ must also exist. As a result, we can apply the matrix identity to the previous expression.
\begin{equation}
\begin{split}
A & = ((C^{T})(X^{T}XC))^{-1}C^{T}X^{T}y \\
& = (X^{T}XC)^{-1}(C^{T})^{-1}C^{T}X^{T}y\\
&=C^{-1}(X^{T}X)^{-1}X^{T}y\\
&=C^{-1}\hat{w}
\end{split}
\end{equation}
To prove that the scaled solution is optimal, we apply Equation 1 and w as follows.
Recall that $(A^{-1})^{T} = (A^{T})^{-1}$. As a result, $(C^{-1})^{T} = (C^{T})^{-1}$. Since $C$ is a real, symmetric matrix, $C=C^{T}$ and, as a result, $(C^{-1})^{T}C=I$.
\begin{center}
$\hat{w}^{T}x=\hat{\tilde{x}}^T\tilde{x}$
\end{center}
\pagebreak
\section*{Problem4}
we can solve for the least squares polynomial regression coefficients $\hat{w}$ by using the extended design matrix $\tilde{X}$ such that
\begin{center}
$\hat{w}=(\tilde{X}^{T}\tilde{X})^{-1}\tilde{X}^{T}y$, where \(\tilde{X}=
\begin{bmatrix}
1& x_1& x_1^2 & \cdots &x_1^d \\
1& x_2 & x_2^2 & \cdots & x_2^d \\
\vdots&\vdots &\vdots& \ddots &\vdots \\
1& x_N & x_N^2 & \cdots & x_N^d
\end{bmatrix}
\)
\end{center}
where $d$ is the degree of the polynomial and ${x_1, ....., x_N}$ and $y$ are the observed points and their
associated labels, respectively. To prevent numerical round-off errors, this method was applied to
the column-normalized design matrix $\tilde{X}$ using degexpand.m within the main script prob5.m (as
discussed in Problem 2). The resulting linear and quadratic polynomials are shown in Figure 2(a).
The fitting parameters obtained using all data points and up to a fourth-order polynomial are
tabulated below.
\begin{table}[h]
\centering
\begin{tabular}{c|c|c|c}
\hline
Polynomial Degree & Empirical Loss & Log-likelihood&10-fold Cross Validation Score
\\\hline
Linear (d = 1) &1.057 &-529.5 &1.063\\
Quadratic (d = 2) &0.930 &-506.1 &0.943\\
Cubic (d = 3) &0.930 &-506.1 &0.947\\
Quartic (d = 4)& 0.925& -505.1 &0.950
\\\hline
\end{tabular}
\end{table}
Note that the empirical loss $L_N$ is defined to be the average sum of squared errors as given by
Equation 9. The log-likelihood of the data (under a Gaussian model) was derived in class on
9/11/06 and is given by Equation 7 as
$l(Y;w,\sigma)=-\frac{1}{2\sigma^2}\sum\limits_{i=1}^N(y_i-f(x_i:w)^2-N\log(\sigma\sqrt{2\pi})$
where $\sigma\rightarrow\hat{\sigma}_{ML}$ is the maximum likelihood estimate of ¾ under a Gaussian noise model (as given
by Equation 8 in Problem 3).
At this point, we turn our attention to the model-order selection task (i.e., deciding what degree
of polynomial best-represents the data). As discussed in class of 9/13/06, we will use 10-fold cross
validation to select the best model. First, we partition the data into 10 roughly equal parts (see
lines 65-70 of prob5.m). Next, we perform 10 sequential trials where we train on all but the ith
fold of the data and then measure the empirical error on the remaining samples. In general, we
formulate the k-fold cross validation score as
\begin{center}
$\hat{L}_k = \frac{1}{N}\sum\limits_{i=1}^k\sum\limits_{j\in fold\, i}(y_i-f(x_j;\hat{w}_i)^2$
\end{center}
where $\hat{w}_i$ is fit to all samples except those in the $i^{th}$ fold. The resulting 10-fold cross-validation
scores are tabulated above (for up to a fourth-order polynomial). Since the lowest cross-validation
score is achieved for the quadratic polynomial we select this as the best model.
In conclusion, we ¯nd that the quadratic polynomial has the lowest cross-validation score.
However, as shown in Figure 2(b), it is immediately apparent that the Gaussian noise model does
not accurately represent the underlying distribution; more specifically, if the underlying distribution
was Gaussian, we'd expect half of the data points to be above the model prediction (and the other
half below). This is clearly not the case for this example { motivating the alternate noise model
we'll analyze in Problem 6.
\pagebreak
\section*{Problem5}
Part 1: Consider the noise model $y = f(x;w) + v$ in which $v$ is drawn from $p(v)$ as follows.
\[
p(v)=\left\{
\begin{array}{ll}
e^{-v}\,\,\,\, if\,v>0,\\
0\,\,\,\,\,\,\,\,\,\, otherwise
\end{array}
\right.
\]
Perform 10-fold cross-validation for linear and quadratic regression under this noise model, using
exhaustive numerical search similar to that used in Problem 4. Plot the selected model and report
the empirical loss and the log-likelihood under the estimated exponential noise model.
let's begin by defining the distribution of the label $y$, given the input $x$.
\[
p(y|x,w)=\left\{
\begin{array}{ll}
\exp(-(y-f(x;w))){-v}\,\,\,\, if\,y>f(x;w),\\
0\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\, otherwise
\end{array}
\right.
\]
Once again, we assume that the observations are i.i.d. such that the likelihood $P$ is given as follows.
\[
P(Y;w)=\prod\limits^N_{i=1}p(y_i|x_i, w)=\prod\limits^N_{i=1}\left\{
\begin{array}{ll}
\exp(f(x_i;w)-y_i)\,\,\,\, if\,y_i>f(x;w),\\
0\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\, otherwise
\end{array}
\right.
\]
The log-likelihood $l$ is then given by
\[
l(Y;w)=\log{P}(Y;w)=\sum\limits^N_{i=1}\left\{
\begin{array}{ll}
\exp(f(x_i;w)-y_i)\,\,\,\, if\,y_i>f(x_i;w),\\
\infty\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\, otherwise
\end{array}
\right.
\]
since the logarithm is a monotonic function and $\lim_{x\to\infty} \log{x}=-\infty$.The corresponding ML
estimate for $w$ is given by the following expression.
\[
\hat{w}_{ML}=\arg\max_{w}(Y;w)=\arg\min_{w}\sum\limits^N_{i=1}\left\{
\begin{array}{ll}
\exp(y_i-f(x_i;w))\,\,\,\, if\,y_i>f(x_i;w),\\
\infty\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\,\, otherwise
\end{array}
\right.
\]
Note that Equations 10 and 11 prevent any prediction $f(x_i; w)$ from being above the corresponding label $y_i$. As a result, the exponential noise distribution will effectively lead to a model corresponding to the lower-envelope of the training data.
Using the maximum likelihood formulation in Equation 12, we can solve for the optimal regression parameters using an exhaustive search (similar to what was done in Problem 4). This
approach was applied to all the data points on lines 19-72 of prob6.m. The resulting best-fit linear and quadratic polynomial models are shown in Figure 3(a). The fitting parameters obtained using all the data points and up to a second-order polynomial are tabulated below.
\begin{table}[h]
\centering
\begin{tabular}{c|c|c|c}
\hline
Polynomial Degree & Empirical Loss & Log-likelihood&10-fold Cross Validation Score
\\\hline
Linear (d = 1) &2.837 &-487.5 &2.837\\
Quadratic (d = 2) &1.901 &-359.1 &1.900
\\\hline
\end{tabular}
\end{table}
Note that the empirical loss $L_N$ was calculated using Equation 9. The log-likelihood of the data
(under the exponential noise model) was determined using Equation 11.
Model selection was performed using 10-fold cross-validation as in Problem 5. The resulting
scores are tabulated above. Since the lowest cross-validation score was achieved for the quadratic polynomial we select this as the best model and plot the result in Figure 3(b). Comparing the model in Figure 3(b) with that in Figure 2(b), we conclude that the quadratic polynomial under the exponential noise model better approximates the underlying distribution; more specifically, the quadratic polynomial (under an exponential noise model) achieves a log-likelihood of -359.2, whereas it only achieves a log-likelihood of -506.1 under the Gaussian noise model. It is also important to note that the Gaussian noise model leads to a lower squared loss (i.e., empirical loss), however this is by the construction of the least squares estimator used in Problem 5. This highlights the important observation that a lower empirical loss does not necessarily indicate a better model -this only applies when the choice of noise model appropriately models the actual distribution.
Part 2: Now evaluate the polynomials selected under the Gaussian and exponential noise models for the data in 2005. Report which performs better in terms of likelihood and empirical loss.
In both Problems 5 and 6.1, the quadratic polynomial was selected as the best model by 10-fold
cross validation. In order to gauge the generalization capabilities of these models, the 2004 model parameters we used to predict the 2005 samples. The results for each noise model are tabulated below.
\begin{table}[h]
\centering
\begin{tabular}{c|c|c}
\hline
Noise Model & Empirical Loss & Log-likelihood
\\\hline
Gaussian (d = 2) &2.837 &2.837\\
Exponential (d = 2) &1.901 &1.900
\\\hline
\end{tabular}
\end{table}
In conclusion, we find that the Gaussian model achieves a lower empirical loss on the 2005 samples. This is expected, since the Gaussian model is equivalent to the least squares estimator which minimizes empirical loss. The exponential model, however, achieves a significantly higher log-likelihood - indicating that it models the underlying data more effectively than the Gaussian noise model. As a result, we reiterate the point made previously: low empirical loss can be achieved even if the noise model does not accurately represent the underlying noise distribution.
\end{document}
```

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