Inference for difference in two means
Inference for a proportion
Inference for difference in two proportions
Reminder - HW4 due on Tuesday 11/15 by 11 pm (repos on Github)
2010 GSS:
gss = read.csv("https://stat.duke.edu/~mc301/data/gss2010.csv")
Is there a difference between the average number of hours relaxing after work between males and females. What are the hypotheses?
\[H_0: \mu_{M} = \mu_{F}\] \[H_A: \mu_{M} \ne \mu_{F}\]
Note that the variable identifying males and females in the dataset is sex
.
What type of visualization would be appropriate for evaluating this research question?
(hrsrelax_sex_summ = gss %>% filter(!is.na(hrsrelax)) %>% group_by(sex) %>% summarise(xbar = mean(hrsrelax), s = sd(hrsrelax), n = length(hrsrelax)))
## # A tibble: 2 × 4 ## sex xbar s n ## <fctr> <dbl> <dbl> <int> ## 1 FEMALE 3.449180 2.396948 610 ## 2 MALE 3.939338 2.848216 544
\[ \begin{aligned} t &= \frac{obs - null}{SE} = \frac{(\bar{x}_1-\bar{x}_2) - 0}{\sqrt{s^2_1/n_1+s^2_2/n_2}} \sim T_{df} \\ df &\approx \frac{(s_1^2/n_1+s_2^2/n_2)^2}{(s_1^2/n_1)^2/(n_1-1)+(s_2^2/n_2)^2/(n_2-1)} \approx min(n_1 - 1, n_2 - 1) \end{aligned} \]
(se = sqrt((hrsrelax_sex_summ$s[1]^2 / hrsrelax_sex_summ$n[1]) + (hrsrelax_sex_summ$s[2]^2 / hrsrelax_sex_summ$n[2])))
## [1] 0.155984
(t = ((hrsrelax_sex_summ$xbar[1] - hrsrelax_sex_summ$xbar[2]) - 0) / se)
## [1] -3.14236
(df = min(hrsrelax_sex_summ$n[1], hrsrelax_sex_summ$n[2]) - 1)
## [1] 543
p-value = P(observed or more extreme outcome | \(H_0\) true)
pt(t, df) * 2
## [1] 0.001767347
pt(t, df) + pt(-t, df, lower.tail=FALSE)
## [1] 0.001767347
What is the equivalent confidence level to this hypothesis test? At this level would you expect a confidence interval to include the difference in average number of hours relaxed by all American males and females?
\[point~estimate \pm critical~value \times SE\] \[(\bar{x}_1-\bar{x}_2) \pm t^* \times \sqrt{s^2_1/n_1+s^2_2/n_2} \]
(t_star = qt(0.975, df))
## [1] 1.964342
(pt_est = hrsrelax_sex_summ$xbar[1] - hrsrelax_sex_summ$xbar[2])
## [1] -0.4901579
round(pt_est + c(-1,1) * t_star * se, 3)
## [1] -0.797 -0.184
Note that t.test
function uses an exact degrees of freedom formula not \(\min(n_1-1,n_2-1)\).
# HT t.test(gss$hrsrelax ~ gss$sex, mu = 0, alternative = "two.sided")
## ## Welch Two Sample t-test ## ## data: gss$hrsrelax by gss$sex ## t = -3.1424, df = 1066.3, p-value = 0.001722 ## alternative hypothesis: true difference in means is not equal to 0 ## 95 percent confidence interval: ## -0.7962283 -0.1840875 ## sample estimates: ## mean in group FEMALE mean in group MALE ## 3.449180 3.939338
t.test(gss$hrsrelax ~ gss$sex)$conf.int
## [1] -0.7962283 -0.1840875 ## attr(,"conf.level") ## [1] 0.95
## Response variable: numerical ## Explanatory variable: categorical (2 levels) ## n_MALE = 544, y_bar_MALE = 3.9393, s_MALE = 3 ## n_FEMALE = 610, y_bar_FEMALE = 3.4492, s_FEMALE = 3 ## H0: mu_MALE = mu_FEMALE ## HA: mu_MALE != mu_FEMALE ## p_value = 9e-04
## Response variable: numerical, Explanatory variable: categorical (2 levels) ## n_MALE = 544, y_bar_MALE = 3.9393, s_MALE = 2.8482 ## n_FEMALE = 610, y_bar_FEMALE = 3.4492, s_FEMALE = 2.3969 ## 95% CI (MALE - FEMALE): (0.1838 , 0.7939)
Another question on the survey is "Do you think the use of marijuana should be made legal or not?". Do these data convincing evidence that majority of Americans think that the use of marijuana should not be legal? Note that the variable of interest in the dataset is grass
.
(grass_summ = gss %>% filter(!is.na(grass)) %>% summarise(x = sum(grass == "NOT LEGAL"), n = length(grass), p_hat = x / n))
## x n p_hat ## 1 656 1259 0.5210485
What are the hypotheses?
Let \(p\) be the proportion of all americans who do not think marijuana should be legalized.
\[H_0: p = 0.5\] \[H_A: p > 0.5\]
\[Z = \frac{obs - null}{SE} = \frac{\hat{p} - p_0}{\sqrt{\frac{p_0 (1-p_0)}{n}}} \sim N(0,1)\]
p_0 = 0.5 (se = sqrt(p_0 * (1-p_0) / grass_summ$n))
## [1] 0.0140915
(Z = (grass_summ$p_hat - p_0) / se)
## [1] 1.493699
p-value = \(P(\text{observed or more extreme outcome}~|~H_0~\text{true})\)
pnorm(Z, lower.tail = FALSE)
## [1] 0.06762719
\[point~estimate \pm critical~value \times SE\] \[ \hat{p} \pm z^* \times \sqrt{\frac{\hat{p} (1-\hat{p})}{n}} \]
(z_star = qnorm(0.95))
## [1] 1.644854
(se = sqrt(grass_summ$p_hat * (1 - grass_summ$p_hat) / grass_summ$n))
## [1] 0.01407901
round(grass_summ$p_hat + c(-1,1) * z_star * se, 3)
## [1] 0.498 0.544
Note that prop.test
function uses a different (equivalent) distribution.
prop.test(grass_summ$x, grass_summ$n, p = 0.5, alternative = "greater", correct = FALSE)
## ## 1-sample proportions test without continuity correction ## ## data: grass_summ$x out of grass_summ$n, null probability 0.5 ## X-squared = 2.2311, df = 1, p-value = 0.06763 ## alternative hypothesis: true p is greater than 0.5 ## 95 percent confidence interval: ## 0.4978702 1.0000000 ## sample estimates: ## p ## 0.5210485
prop.test(grass_summ$x, grass_summ$n, correct = FALSE, conf.level = 0.90)$conf.int
## [1] 0.4978702 0.5441364 ## attr(,"conf.level") ## [1] 0.9
## Single categorical variable, success: NOT LEGAL ## n = 1259, p-hat = 0.521 ## H0: p = 0.5 ## HA: p > 0.5 ## p_value = 0.0717
## Single categorical variable, success: NOT LEGAL ## n = 1259, p-hat = 0.521 ## 95% CI: (0.4932 , 0.5488)
Is there a difference between the proportions of people who think marijuana should not be legalized based on whether they favor or oppose a law which would require a person to obtain a police permit before he or she could buy a gun?
Let \(p\) represent people who do not think marijuana should be legalized.
\[H_0: p_{not~legal|favor~gunlaw} = p_{not~legal|oppose~gunlaw}\] \[H_A: p_{not~legal|favor~gunlaw} \ne p_{not~legal|oppose~gunlaw}\]
Note that the variable identifying people who are pro and anti gun laws in the dataset is gunlaw
.
What type of visualization would be appropriate for evaluating this research question?
table(gss$gunlaw, gss$grass) %>% addmargins()
## ## LEGAL NOT LEGAL Sum ## FAVOR 209 211 420 ## OPPOSE 70 65 135 ## Sum 279 276 555
(gss_gun_grss_summ = gss_gun_grss %>% group_by(gunlaw) %>% summarise(x = sum(grass == "NOT LEGAL"), n = length(grass), p_hat = x / n))
## # A tibble: 2 × 4 ## gunlaw x n p_hat ## <fctr> <int> <int> <dbl> ## 1 FAVOR 211 420 0.5023810 ## 2 OPPOSE 65 135 0.4814815
\[(\hat{p}_1 - \hat{p}_2) \sim N\left(mean = (p_1 - p_2),~SE = \sqrt{ \frac{p_1 (1 - p_1)}{n_1} + \frac{p_2 (1 - p_2)}{n_2} } \right)\] \[Z = \frac{obs - null}{SE} = \frac{(\hat{p}_1 - \hat{p}_2) - 0}{\sqrt{ \frac{p_1 (1 - p_1)}{n_1} + \frac{p_2 (1 - p_2)}{n_2} }}\]
We need to find a reasonable value for \(p_1\) and \(p_2\) that are equal to each other, and that make sense in the context of these data.
Remember the null hypothesis is equivalent to claiming the two variables are independent.
LEGAL | NOT LEGAL | Sum | |
---|---|---|---|
FAVOR | 209 | 211 | 420 |
OPPOSE | 70 | 65 | 135 |
Sum | 279 | 276 | 555 |
(p_pool = 276 / 555)
## [1] 0.4972973
(se = sqrt( (p_pool * (1-p_pool))/gss_gun_grss_summ$n[1] + (p_pool * (1-p_pool))/gss_gun_grss_summ$n[2] ) )
## [1] 0.04946735
(Z = ((gss_gun_grss_summ$p_hat[1] - gss_gun_grss_summ$p_hat[2]) - 0) / se)
## [1] 0.4224902
p-value = P(observed or more extreme outcome | \(H_0\) true)
pnorm(Z, lower.tail= FALSE) * 2
## [1] 0.6726672
What is the equivalent confidence level to this hypothesis test? At this level would you expect a confidence interval to include 0?
\[point~estimate \pm critical~value \times SE\]
\[(\hat{p}_1-\hat{p}_2) \pm Z^* \times \sqrt{ \frac{\hat{p}_1 (1 - \hat{p}_1)}{n_1} + \frac{\hat{p}_2 (1 - \hat{p}_2)}{n_2} } \]
The only difference is that SE is calculated using the sample proportions, and not the pooled proportion.
(z_star = qnorm(0.95))
## [1] 1.644854
p1 = gss_gun_grss_summ$p_hat[1]; n1 = gss_gun_grss_summ$n[1] p2 = gss_gun_grss_summ$p_hat[2]; n2 = gss_gun_grss_summ$n[2] pt_est = p1 - p2 (se = sqrt(p1*(1-p1)/n1 + p2*(1-p2)/n2))
## [1] 0.04944225
round(pt_est + c(-1,1) * z_star * se, 3)
## [1] -0.060 0.102
prop.test(x = c(gss_gun_grss_summ$x[1], gss_gun_grss_summ$x[2]), n = c(gss_gun_grss_summ$n[1], gss_gun_grss_summ$n[2]), correct = FALSE)
## ## 2-sample test for equality of proportions without continuity ## correction ## ## data: c(gss_gun_grss_summ$x[1], gss_gun_grss_summ$x[2]) out of c(gss_gun_grss_summ$n[1], gss_gun_grss_summ$n[2]) ## X-squared = 0.1785, df = 1, p-value = 0.6727 ## alternative hypothesis: two.sided ## 95 percent confidence interval: ## -0.07600556 0.11780450 ## sample estimates: ## prop 1 prop 2 ## 0.5023810 0.4814815
## Response variable: categorical (2 levels, success: NOT LEGAL) ## Explanatory variable: categorical (2 levels) ## n_FAVOR = 420, p_hat_FAVOR = 0.5024 ## n_OPPOSE = 135, p_hat_OPPOSE = 0.4815 ## H0: p_FAVOR = p_OPPOSE ## HA: p_FAVOR != p_OPPOSE ## p_value = 0.7339
## Response variable: categorical (2 levels, success: NOT LEGAL) ## Explanatory variable: categorical (2 levels) ## n_FAVOR = 420, p_hat_FAVOR = 0.5024 ## n_OPPOSE = 135, p_hat_OPPOSE = 0.4815 ## 95% CI (FAVOR - OPPOSE): (-0.0751 , 0.118)
We now have been introduced to both simulation based and CLT based methods for statistical inference.
For most simulation based methods you wrote your own code, for CLT based methods we introduced some built in functions.
Take away message: If certain conditions are met CLT based methods may be used for statistical inference. To do so, we would need to know how the standard error is calculated for the given sample statistic of interest.