Solutions to Exercises in Chapter 5 29 (c) The 95 confidence 30 Stock/ Watson - Introduction to Econometrics - Second Edition 5 (a) The estimated gain
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Chapter 5
Regression with a Single Regressor:
Hypothesis Tests and Confidence Intervals
Solutions to Exercises
1 (a) The 95% confidence interval for
1β is { 5 82 1 96 2 21},-. ±. ×. that is
1 (b) Calculate the t-statistic: 1 1ˆ058226335ˆSE( ) 2 21
act tThe p-value for the test
010Hβ:= vs.
110Hβ:≠ is
-value 2 ( | |) 2 ( 2 6335) 2 0 0042 0 0084 act pt=Φ- =Φ-. =×. =. . The p-value is less than 0.01, so we can reject the null hypothesis at the 5% significance level, and also at the 1% significance level. (c) The t-statistic is 1 1ˆ( 5.6)0220.10ˆSE( ) 2 21
act tThe p-value for the test
01 :5.6Hβ=- vs. 11 :5.6Hβ≠- is -value 2 ( | |) 2 ( 0.10) 0.92 act pt=Φ- =Φ- = The p-value is larger than 0.10, so we cannot reject the null hypothesis at the 10%, 5% or 1% significance level. Because15.6β=- is not rejected at the 5% level, this value is contained in
the 95% confidence interval. (d) The 99% confidence interval for 0 is {520.4 2.58 20.4},±× that is, 02. (a) The estimated gender gap equals $2.12/hour.
(b) The hypothesis testing for the gender gap is 010Hβ:= vs.
110.Hβ:≠ With a t-statistic
1 1ˆ02.125.89ˆ()036
act tSE the p-value for the test is -value 2 ( | |) 2 ( 5.89) 2 0 0000 0 000 act pt=Φ- =Φ- =×. =. (to four decimal places) The p-value is less than 0.01, so we can reject the null hypothesis that there is no gender gap at a1% significance level.
Solutions to Exercises in Chapter 5 29
(c) The 95% confidence interval for the gender gap 1β is {2 12 1 96 0 36},.±.×. that is,
1 (d) The sample average wage of women is 0ˆ12 52/hour.$
β=. The sample average wage of men is
01ˆˆ$12.52 $2.12 $14.64/hour.
(e) The binary variable regression model relating wages to gender can be written as either 01iWage Male uββ=+ +,
or 01iWage Female vγγ=+ +.
In the first regression equation,
Male equals 1 for men and 0 for women;
0β is the population
mean of wages for women and 01 ββ+ is the population mean of wages for men. In the second regression equation,Female equals 1 for women and 0 for men;
0γ is the population mean of
wages for men and 01 γγ+ is the population mean of wages for women. We have the following relationship for the coefficients in the two regression equations: 001 01 0Given the coefficient estimates
0 and 1 , we have 001 10 01ˆˆˆ14.64
ˆˆ212
Due to the relationship among coefficient estimates, for each individual observation, the OLS residual is the same under the two regression equations: . iiuv=Thus the sum of squared residuals, 2 1 n i i SSRu is the same under the two regressions. This implies that both 1 2 1SSR n SER = and 2 1 SSR TSSR=- are unchanged.
In summary, in regressing Wages on
,Female we will get14.64 2 12Wages Female=-. ,
2006 SER 4.2R=. , = .
4. (a) -3.13 + 1.47 × 16 = $20.39 per hour
(b) The wage is expected to increase from $14.51 to $17.45 or by $2.94 per hour. (c) The increase in wages for college education is 1× 4. Thus, the counselor's assertion is that
1 = 10/4 = 2.50. The t-statistic for this null hypothesis is1.47 2.50
0.0714.71,t
=- which has a p-value of 0.00. Thus, the counselor's assertion can be rejected at the 1% significance level. A95% confidence for
130 Stock/Watson - Introduction to Econometrics - Second Edition
5 (a) The estimated gain from being in a small class is 13.9 points. This is equal to approximately 1/5
of the standard deviation in test scores, a moderate increase. (b) The t-statistic is 13.9 2.5 5.56, act t== which has a p-value of 0.00. Thus the null hypothesis is rejected at the 5% (and 1%) level. (c) 13.9± 2.58 × 2.5 = 13.9 ± 6.45.
6. (a) The question asks whether the variability in test scores in large classes is the same as the
variability in small classes. It is hard to say. On the one hand, teachers in small classes might able
so spend more time bringing all of the students along, reducing the poor performance of particularly unprepared students. On the other hand, most of the variability in test scores might be beyond the control of the teacher.(b) The formula in 5.3 is valid for heteroskesdasticity or homoskedasticity; thus inferences are valid
in either case.7. (a) The t-statistic is
3.2 1.52.13= with a p-value of 0.03; since the p-value is less than 0.05, the null
hypothesis is rejected at the 5% level. (b) 3.2 ± 1.96 × 1.5 = 3.2 ± 2.94 (c) Yes. If Y and X are independent, then 1 = 0; but this null hypothesis was rejected at the 5% level in part (a). (d) 1 would be rejected at the 5% level in 5% of the samples; 95% of the confidence intervals would contain the value 1 = 0.8. (a) 43.2 ± 2.05 × 10.2 or 43.2 ± 20.91, where 2.05 is the 5% two-sided critical value from the t
28distribution. (b) The t-statistic is
61.5 55
7.4 0.88, act t == which is less (in absolute value) than the critical value of20.5. Thus, the null hypothesis is not rejected at the 5% level.
(c) The one sided 5% critical value is 1.70; t act is less than this critical value, so that the null hypothesis is not rejected at the 5% level.9. (a)
11 12 nXnYY Yβ= +++? so that it is linear function of Y
1 , Y 2 , ..., Y n (b) E(Y i |X 1 , ..., X n 1 X i , thus 112111 1
11(|,,) ( )|,,)
11 nnn nEX X E YY YX XXn
XXXnβ
10. Let n
0 denote the number of observation with X = 0 and n 1 denote the number of observations withX = 1; note that
11 n i i Xn 1 |;Xnn= 1 1 11 n ii ni XY Y 21011222
1111
() 1 ; nnnnnn ii nnnii
XX XnX n n
11 001
n i i nY nY Y so that 01 10n n nn YYY=+Solutions to Exercises in Chapter 5 31
From the least squares formula
1111122
1110
0 1 11010
00 nnn ii i iii iii nn ii ii
XXYY XYY XYYn
XX XX nnn
nnnnYY Y Y Y YYnnnn and 0101101 0110 00
ˆˆ()nnnnnYX Y YYY YYnn nn
11. Using the results from 5.10,
0 mYβ= and
1 wmYYβ=- From Chapter 3, SE( )
m m S m nY= and
22SE( ) .
mw mw ss wm nnYY-= + Plugging in the numbers
0ˆ523.1
β= and
01ˆˆSE( ) 6.22; 38.0
ββ==- and
1ˆSE( ) 7.65.
12. Equation (4.22) gives
0 2ˆ222
var( )where 1 ii x ii iiHuHXEXnEH
Using the facts that ( | ) 0
iiEuX= and var
2 ii u uXσ= (homoskedasticity), we have 222 000 xx ii i ii i i i i ii x i
EHu Eu Xu Eu EXEuXEX EX
EX and 2 2 2 2 222222
2 22
2 2 2 2| x ii i ii i xx iii ii ii x xiiii i i
EHu Eu XuEX
Eu Xu Xu
EX EXEu EXEu X
EXEX 222 2 22 2
2 2 2 2 2 2 1. iii x xiuxu u i i x u i
EXEu X
EX EXEX EXBecause ( ) 0,
iiEHu= var
2 ii iiHu E Hu=,so
32 Stock/Watson - Introduction to Econometrics - Second Edition
2 222 var( ) [( ) ] 1 x ii ii u i
Hu E HuEX
We can also get
2222
222
2 222
22
2 112
12 1 xxx ii ii iii xx xi ii i