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Consider the general linear model $$Y=\beta_{0}+\beta_{1} x_{1}+\beta_{2} x_{2}+\cdots+\beta_{k} x_{k}+\varepsilon$$ where \(E(\varepsilon)=0\) and \(V(\varepsilon)=\sigma^{2} .\) Notice that \(\widehat{\beta}_{i}=\mathbf{a}^{\prime} \hat{\boldsymbol{\beta}},\) where the vector a is defined by $$a_{j}=\left\\{\begin{array}{ll} 1, & \text { if } j=i, \\ 0, & \text { if } \neq i \end{array}\right.$$ Use this to verify that \(E\left(\widehat{\beta}_{i}\right)=\beta_{i}\) and \(V\left(\widehat{\beta}_{i}\right)=c_{i i} \sigma^{2},\) where \(c_{i i}\) is the element in row \(i\) and column \(i\) of \(\left(\mathbf{x}^{\prime} \mathbf{x}\right)^{-1}\)

Short Answer

Expert verified
The expected value is \( E(\widehat{\beta}_{i}) = \beta_{i} \) and the variance is \( V(\widehat{\beta}_{i}) = c_{i i} \sigma^{2} \).

Step by step solution

01

Express \( \widehat{\beta}_{i} \)

Start from the expression for \( \widehat{\beta}_{i} \): \( \widehat{\beta}_{i} = \mathbf{a}^{\prime} \hat{\boldsymbol{\beta}} \). The vector \( \mathbf{a} \) is defined such that all elements are 0 except for the \( i^{th} \) element, which is 1. Then, \( \widehat{\beta}_{i} \) is simply the \( i^{th} \) element of \( \hat{\boldsymbol{\beta}} \).
02

Express \( \hat{\boldsymbol{\beta}} \)

Recall that \( \hat{\boldsymbol{\beta}} = (\mathbf{x}^{\prime} \mathbf{x})^{-1} \mathbf{x}^{\prime} \mathbf{Y} \). This estimate is derived using the normal equation in linear regression, where \( \mathbf{x} \) is the matrix of predictors.
03

Calculate \( E(\widehat{\beta}_{i}) \)

Using the expectation, find \( E(\widehat{\beta}_{i}) = \mathbf{a}^{\prime} E(\hat{\boldsymbol{\beta}}) \). Since \( E(\hat{\boldsymbol{\beta}}) = \boldsymbol{\beta} \) based on the assumed properties of the error term \( \varepsilon \), it follows that \( E(\widehat{\beta}_{i}) = \mathbf{a}^{\prime} \boldsymbol{\beta} = \beta_{i} \).
04

Calculate \( V(\widehat{\beta}_{i}) \)

For the variance, use the property \( V(\widehat{\beta}_{i}) = \mathbf{a}^{\prime} V(\hat{\boldsymbol{\beta}}) \mathbf{a} \). Then, \( V(\hat{\boldsymbol{\beta}}) = \sigma^{2} (\mathbf{x}^{\prime} \mathbf{x})^{-1} \). So, \( V(\widehat{\beta}_{i}) = \mathbf{a}^{\prime} \sigma^{2} (\mathbf{x}^{\prime} \mathbf{x})^{-1} \mathbf{a} = \sigma^{2} c_{i i} \), where \( c_{i i} \) is the \( i^{th} \) diagonal element of \( (\mathbf{x}^{\prime} \mathbf{x})^{-1} \).

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Key Concepts

These are the key concepts you need to understand to accurately answer the question.

General Linear Model
The General Linear Model (GLM) is a powerful mathematical tool used to describe the relationship between a dependent variable and several independent variables. It forms the backbone of linear regression analysis. In a typical GLM, the relationship is expressed using a linear equation:\[ Y = \beta_{0} + \beta_{1}x_{1} + \beta_{2}x_{2} + \cdots + \beta_{k}x_{k} + \varepsilon \]Here, \(Y\) is the output or response variable. The terms \(\beta_{0}, \beta_{1}, \ldots, \beta_{k}\) are coefficients that need to be estimated, and they represent the strength and direction of the relationship between each predictor \(x_{i}\) and the response \(Y\). The \(\varepsilon\) signifies the error term or residual, capturing the part of \(Y\) not explained by the linear combination of predictors.
  • **Interpreting \(\varepsilon\)**: \(E(\varepsilon) = 0\) indicates that the errors have a mean of zero, suggesting no systematic bias in the predictions.
  • **Variance of \(\varepsilon\)**: \(V(\varepsilon) = \sigma^{2}\) reflects how scattered the error values are. The lower the \(\sigma^{2}\), the better the model explains the variability in \(Y\).
Understanding the GLM allows statisticians and data scientists to make inferences about the relationships between variables and predict new outcomes effectively.
Estimation
Estimation is the process of determining the values of the coefficients \(\beta_{i}\) in the general linear model. The most common technique for estimation in linear regression is the **Ordinary Least Squares (OLS)** method. This method seeks to find the set of coefficients that minimize the sum of squared differences between observed values and those predicted by the model.
  • The point estimates \(\widehat{\beta}_{i}\) are calculated using the formula: \(\widehat{\beta} = (\mathbf{x}^{\prime} \mathbf{x})^{-1} \mathbf{x}^{\prime} \mathbf{Y}\).
  • This equation leverages the **normal equations** derived from calculus to arrive at the least squares solution that minimizes prediction errors.
Once these coefficients are estimated, the model can be used to predict new response values and understand the strength and importance of each predictor variable. Accurate estimation is crucial for making valid predictions and interpretations from the linear model.
Variance
Variance in the context of linear regression is a measure of how much the estimates of the coefficients vary. It's crucial because it helps assess the reliability and precision of the model's predictions.In our scenario:\[ V(\widehat{\beta}_{i}) = \sigma^{2}c_{ii} \]Here, \(c_{ii}\) is derived from the matrix \((\mathbf{x}^{\prime} \mathbf{x})^{-1}\), and it represents the diagonal elements related to the predictors. This formula shows that the variance of \(\widehat{\beta}_{i}\) depends not only on the noise \(\sigma^{2}\) but also on the specific data structure captured by \(c_{ii}\).
  • **Lower variance**: Implies a more certain estimate of \(\beta_{i}\). It's desirable as it indicates that the coefficient is stable across samples.
  • **Larger \(c_{ii}\)**: Means less information is available about \(\beta_{i}\), likely due to less data or higher correlation between predictors.
Understanding and minimizing the variance of estimates enhance the robustness of the linear model.
Expectation
Expectation in statistics provides a valuable insight into what the average outcome of a given random variable is when repeated many times. For estimators like \(\widehat{\beta}_{i}\), expectation tells us about the estimator's accuracy.For the linear regression estimator, we derive the expectation as follows:\[ E(\widehat{\beta}_{i}) = \beta_{i} \]This equation indicates that our estimator \(\widehat{\beta}_{i}\) is unbiased, meaning on average, it correctly estimates the true parameter value \(\beta_{i}\). It suggests:
  • **Unbiased estimators**: They do not systematically overestimate or underestimate the true parameter. Hence, repeated sampling will average out to the true parameter value.
  • **Reliability**: Computed over a sufficiently large dataset, our estimates are trustworthy and indicative of the true relationship.
Understanding expectation fosters confidence in statistical models as it ensures that our predictions and inferences based on those models are grounded in truth aligned with reality.

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Most popular questions from this chapter

Utility companies, which must plan the operation and expansion of electricity generation, are vitally interested in predicting customer demand over both short and long periods of time. A short-term study was conducted to investigate the effect of each month's mean daily temperature \(x_{1}\) and of cost per kilowatt-hour, \(x_{2}\) on the mean daily consumption (in \(\mathrm{kWh}\) ) per household. The company officials expected the demand for electricity to rise in cold weather (due to heating), fall when the weather was moderate, and rise again when the temperature rose and there was a need for air conditioning. They expected demand to decrease as the cost per kilowatt-hour increased, reflecting greater attention to conservation. Data were available for 2 years, a period during which the cost per kilowatt-hour \(x_{2}\) increased due to the increasing costs of fuel. The company officials fitted the model $$Y=\beta_{0}+\beta_{1} x_{1}+\beta_{2} x_{1}^{2}+\beta_{3} x_{2}+\beta_{4} x_{1} x_{2}+\beta_{5} x_{1}^{2} x_{2}+\varepsilon$$ to the data in the following table and obtained \(\hat{y}=325.606-11.383 x_{1}+.113 x_{1}^{2}-21.699 x_{2}+.873 x_{1} x_{2}-.009 x_{1}^{2} x_{2}\) with \(\mathrm{SSE}=152.177\) When the model \(Y=\beta_{0}-\beta_{1} x_{1}+\beta_{2} x_{1}^{2}+\varepsilon\) was fit, the prediction equation was \(\hat{y}=130.009-3.302 x_{1}+.033 x_{1}^{2}\) with \(\mathrm{SSE}=465.134 .\) Test whether the terms involving \(x_{2}\left(x_{2}, x_{1} x_{2}, x_{1}^{2} x_{2}\right)\) contribute to a significantly better fit of the model to the data. Give bounds for the attained significance level.

The correlation coefficient for the heights and weights of ten offensive backfield football players was determined to be \(r=.8261\) a. What percentage of the variation in weights was explained by the heights of the players? b. What percentage of the variation in heights was explained by the weights of the players? c. Is there sufficient evidence at the \(\alpha=.01\) level to claim that heights and weights are positively correlated? d. What is the attained significance level associated with the test performed in part (c)?

An experiment was conducted to observe the effect of an increase in temperature on the potency of an antibiotic. Three 1 -ounce portions of the antibiotic were stored for equal lengths of time at each of the following Fahrenheit temperatures: \(30^{\circ}, 50^{\circ}, 70^{\circ},\) and \(90^{\circ} .\) The potency readings observed at the end of the experimental period were as shown in the following table. $$\begin{array}{l|cccc}\text { Potency Readings }(y) & 38,43,29 & 32,26,33 & 19,27,23 & 14,19,21 \\ \hline \text { Temperature }(x) & 30^{\circ} & 50^{\circ} & 70^{\circ} & 90^{\circ}\end{array}$$ a. Find the least-squares line appropriate for this data. b. Plot the points and graph the line as a check on your calculations. c. Calculate \(S^{2}\)

The following model was proposed for testing whether there was evidence of salary discrimination against women in a state university system: $$Y=\beta_{0}+\beta_{1} x_{1}+\beta_{2} x_{2}+\beta_{3} x_{1} x_{2}+\beta_{4} x_{2}^{2}+\varepsilon$$,where \(Y=\) annual salary (in thousands of dollars), \(x_{1}=\left\\{\begin{array}{ll}1, & \text { if female } \\ 0, & \text { if male }\end{array}\right.\) \(x_{2}=\) amount of experience (in years).When this model was fit to data obtained from the records of 200 faculty members, \(\mathrm{SSE}=783.90\). The reduced model \(Y=\beta_{0}+\beta_{1} x_{2}+\beta_{2} x_{2}^{2}+\varepsilon\) was also fit and produced a value of \(\mathrm{SSE}=795.23 .\) Do the data provide sufficient evidence to support the claim that the mean salary depends on the gender of the faculty members? Use \(\alpha=.05\)

Suppose that we have postulated the model $$Y_{i}=\beta_{1} x_{i}+\varepsilon_{i} \quad i=1,2, \dots, n$$ where the \(\varepsilon_{i}\) 's are independent and identically distributed random variables with \(E\left(\varepsilon_{i}\right)=0 .\) Then \(\hat{y}_{i}=\widehat{\beta}_{1} x_{i}\) is the predicted value of \(y\) when \(x=x_{i}\) and \(\mathrm{SSE}=\sum_{i=1}^{n}\left[y_{i}-\widehat{\beta}_{1} x_{i}\right]^{2} .\) Find the least- squares estimator of \(\beta_{1}\). (Notice that the equation \(y=\beta x\) describes a straight line passing through the origin. The model just described often is called the no-intercept model.)

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