# Chapter 4 Regression

## 4.1 Estimating an testing a simple regression model

Regression analysis is done through the lm function, with the following syntax: lm(formula, data,...). The first argument is called formula and expects a symbolic description of your model. I will tell you more about how to specify models with the formula syntax later, when we discuss moderation. For now, a few simple examples will suffice. To specify a simple regression model where you predict a dependent variable y by a predictor x, you would use the formula

y ~ x

On the left-hand side of the formula you need to provide the name of the dependent variable. After the name of the dependent variable, you need to put a tilde (~) (which you can read is “is modelled as a function of”). On the right-hand side, you then provide the name of the predictor. R will automatically include an intercept in the model. In R, the intercept is actually represented as a special predictor which always (for every row in the data set) has the value 1. The formula above is actually interpreted as y ~ x + 1

Because the intercept is included in most models, the authors of R have decided to save the you trouble of typing + 1 in each formula, by making this part of the formula implicit. You can fit a model without an intercept (which is the same as fixing the value of the intercept to 0), by instead of + 1, putting - 1 in the formula, as in

y ~ x - 1

The second argument of the lm function is called data and expects the name of the data.frame in which the variables are stored.

To see how the lm function works in practice, let’s open the trump2016 data provided in the sdamr package. This is the data analysed in Chapter 4 and 5. We open and inspect the data as usual:

library(sdamr)
data("trump2016")
# remove the data from the District of Columbia (Washintgon D.C.)
dat <- subset(trump2016,state != "District of Columbia")
head(dat)
##        state hate_groups population hate_groups_per_million
## 1    Alabama          27    4863300                    5.55
## 2     Alaska           0     741894                    0.00
## 3    Arizona          18    6931071                    2.60
## 4   Arkansas          16    2988248                    5.35
## 5 California          79   39250017                    2.01
## 6   Colorado          16    5540545                    2.89
## 1                               15.4               18.5                62.9
## 2                               29.7               10.4                52.9
## 3                               27.7               17.4                49.5
## 4                               21.8               18.7                60.4
## 5                               32.3               15.4                32.7
## 6                               39.2               11.5                44.4

You can see that there are a number of variables in the dataset (and not all of these were analysed in the book). For more information on the variables in the dataset, you can call the help file with ?trump2016.

Now let’s estimate a simple regression model to predict the percentage of votes for Trump by the number of hate groups per million citizens:

modg <- lm(percent_Trump_votes ~ hate_groups_per_million, data=dat)
modg
##
## Call:
## lm(formula = percent_Trump_votes ~ hate_groups_per_million, data = dat)
##
## Coefficients:
##             (Intercept)  hate_groups_per_million
##                    42.9                      2.3

I’ve named the resulting object modg for MODEL G. You can pick any name you like for R objects. Note that when you just print a fitted linear model (by e.g., typing the name of the object modg), R will show the parameter estimates, but nothing else. You can get the important statistics by calling the summary function on the fitted model:

summary(modg)
##
## Call:
## lm(formula = percent_Trump_votes ~ hate_groups_per_million, data = dat)
##
## Residuals:
##      Min       1Q   Median       3Q      Max
## -14.8206  -5.8570  -0.0529   5.2632  20.7883
##
## Coefficients:
##                         Estimate Std. Error t value Pr(>|t|)
## (Intercept)              42.8968     2.4094  17.804  < 2e-16 ***
## hate_groups_per_million   2.3004     0.6715   3.426  0.00127 **
## ---
## Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
##
## Residual standard error: 9.142 on 48 degrees of freedom
## Multiple R-squared:  0.1965, Adjusted R-squared:  0.1797
## F-statistic: 11.74 on 1 and 48 DF,  p-value: 0.001265

This provides quite a lot of useful information. The output of the summary function consists of four parts:

• Call simply shows you the call to the lm function used to fit the model (including the model formula)
• Residuals shows you some summary statistics for the prediction errors of the estimated model (which are often referred to as residuals)
• Coefficients shows you a table with:
• the name of variable for which the parameter was estimated
• Estimate: the estimated parameters
• Std. Error: the standard error of the estimates (this is the standard deviation of the sampling distribution of the estimates)
• t value: the t statistic of the hypothesis test that the true value of the parameter is equal to 0.
• Pr(>|t|): the p-value, which is the probability that, given that the null hypothesis is true (i.e. the true value of the parameter is equal to 0), you would find a t-statistic at least as extreme as the one computed found for this data.
• Some overall model statistics:
• Residual standard error: this is and unbiased estimate of the standard deviation of the errors.
• Multiple R-squared: the $$R^2$$ or proportion of variance of the dependent variable “explained” by the model.
• Adjusted R-squared: an unbiased estimate of the true value of $$R^2$$
• F-statistic: the results of a model comparison comparing the estimated model (MODEL G) to a MODEL R which only includes an intercept.

## 4.2 Model comparisons

Comparing regression models and computing the $$F$$ statistic can be done through the anova() function. Let’s first estimate a restricted version of MODEL G above where we fix the slope of hate_groups_per_million to 0. This MODEL R is identical to a model with only an intercept. We can estimate this by not providing any predictor names, but now explicitly providing the intercept term 1.

# fit a MODEL R with only an intercept
modr <- lm(percent_Trump_votes ~ 1, data=dat)

We can then compute the $$F$$ test by entering this MODEL R, and the MODEL G we estimated earlier, as arguments in the anova function:

anova(modr,modg)
## Analysis of Variance Table
##
## Model 1: percent_Trump_votes ~ 1
## Model 2: percent_Trump_votes ~ hate_groups_per_million
##   Res.Df    RSS Df Sum of Sq      F   Pr(>F)
## 1     49 4992.2
## 2     48 4011.4  1    980.78 11.736 0.001265 **
## ---
## Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1

the output lists the formula’s of the models we compare, and then provides a table with test results. The columns in this table are * Res.Df: the denominator degrees of freedom, i.e. $$n=-\text{npar}(M)$$ * RSS: the “residual sum of squares” or Sum of Squared Error of the model, i.e. $$\text{SSE}(M)$$ * Df: the numerator degrees of freedom,,i.e. $(G) - (R) * Sum of Sq: the reduction in the Sum of Squared Error, i.e. $$\text{SSE}(R) - \text{SSE}(R)$$ * F: the $$F$$ statistic of the test * Pr(>F): the p-value of the test. We can obtain a test for the intercept by fitting a different MODEL R, now without an intercept, and comparing it to MODEL G # fit a MODEL R without an intercept (through " - 1") modr <- lm(percent_Trump_votes ~ hate_groups_per_million - 1, data=dat) anova(modr,modg) ## Analysis of Variance Table ## ## Model 1: percent_Trump_votes ~ hate_groups_per_million - 1 ## Model 2: percent_Trump_votes ~ hate_groups_per_million ## Res.Df RSS Df Sum of Sq F Pr(>F) ## 1 49 30501.7 ## 2 48 4011.4 1 26490 316.98 < 2.2e-16 *** ## --- ## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1 The output of the anova function isn’t particularly pretty. Also, if you want to do multiple model comparisons, first estimating models and then comparing them with the anova function becomes a little cumbersome. An easier way to obtain all the model comparisons is to use the Anova function from the car package to automatically construct different possible versions of MODEL R, each being one particular restriction of MODEL G which fixes the relevant parameter to 0. If you don’t have the car package installed yet, you need to install it first (e.g. by install.packages("car"). You can then call: library(car) ## Loading required package: carData Anova(modg, type=3) ## Anova Table (Type III tests) ## ## Response: percent_Trump_votes ## Sum Sq Df F value Pr(>F) ## (Intercept) 26490.3 1 316.981 < 2.2e-16 *** ## hate_groups_per_million 980.8 1 11.736 0.001265 ** ## Residuals 4011.4 48 ## --- ## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1 Note that it is important to give the type = 3 argument in the Anova function. This will construct MODEL R by fixing a single parameter to 0 in turn (i.e. first fixing $$\beta_0=0$$ and estimating all other parameters, then another model fixing $$\beta_1 = 0$$ for estimating all other parameters), etc. ## 4.3 Estimating and testing a multiple regression model To specify a multiple regression model for a dependent variable named y and with three predictors, named x1, x2, and x3, you would use the formula y ~ x1 + x2 + x3 This is similar to the earlier formula, but you now need to provide the names of all the predictors, separated by a + sign. For instance, we can fit a model with two predictors (which we will call modg, for MODEL G), as follows: modg <- lm(percent_Trump_votes ~ hate_groups_per_million + percent_bachelors_degree_or_higher, data=dat) summary(modg) ## ## Call: ## lm(formula = percent_Trump_votes ~ hate_groups_per_million + ## percent_bachelors_degree_or_higher, data = dat) ## ## Residuals: ## Min 1Q Median 3Q Max ## -13.7268 -4.0621 0.0426 2.8937 15.8359 ## ## Coefficients: ## Estimate Std. Error t value Pr(>|t|) ## (Intercept) 81.9945 6.1555 13.321 < 2e-16 *** ## hate_groups_per_million 1.3138 0.5102 2.575 0.0132 * ## percent_bachelors_degree_or_higher -1.2187 0.1839 -6.625 3.03e-08 *** ## --- ## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1 ## ## Residual standard error: 6.643 on 47 degrees of freedom ## Multiple R-squared: 0.5845, Adjusted R-squared: 0.5668 ## F-statistic: 33.06 on 2 and 47 DF, p-value: 1.087e-09 the output of the summary function contains the same elements as before, but the table of coefficients now includes an additional row for percent_bachelors_degree_or_higher. Also, note that all the estimates are different, because the slopes reflect unique effects, and these differ compared to models with other predictors. Finally, I’d like to point out that the last row of the output contains the “whole model test,” which compares the estimated model to a model with only an intercept. Recall that the estimate of the intercept in this latter model equals the sample mean. So we are now comparing a model with two predictors to a model which predicts all values as the sample mean. The difference in the number of estimated parameters for this comparison is $$\text{npar}(G) - \text{npar}(R) = 3 - 1 = 2$$. Hence, the degrees of freedom are $$\text{df}_1 = 2$$ and $$\text{df}_2 = n - \text{npar}(G) = 50 - 3 = 47$$. We can also get all the model comparisons for this MODEL G through: Anova(modg, type=3) ## Anova Table (Type III tests) ## ## Response: percent_Trump_votes ## Sum Sq Df F value Pr(>F) ## (Intercept) 7830.7 1 177.4381 < 2.2e-16 *** ## hate_groups_per_million 292.7 1 6.6318 0.01322 * ## percent_bachelors_degree_or_higher 1937.2 1 43.8956 3.028e-08 *** ## Residuals 2074.2 47 ## --- ## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1 Finally, we can also obtain a “whole model test,” by comparing an intercept-only MODEL R to the full MODEL G. This is best done through the anova function as follows: modr <- lm(percent_Trump_votes ~ 1, data=dat) modg <- lm(percent_Trump_votes ~ hate_groups_per_million + percent_bachelors_degree_or_higher, data=dat) anova(modr,modg) ## Analysis of Variance Table ## ## Model 1: percent_Trump_votes ~ 1 ## Model 2: percent_Trump_votes ~ hate_groups_per_million + percent_bachelors_degree_or_higher ## Res.Df RSS Df Sum of Sq F Pr(>F) ## 1 49 4992.2 ## 2 47 2074.2 2 2918 33.06 1.087e-09 *** ## --- ## Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1 ## 4.4 Residuals and predicted values You can obtain the prediction errors by the calling the residuals function on the fitted model. # store the residuals as errorg errorg <- residuals(modg) head(errorg) ## 1 2 3 4 5 6 ## -7.618118 7.101376 -2.152059 -2.055564 -12.570794 6.382163 This returns a vector with, for each case in the data (each row in the data frame), the error term $$\hat{\epsilon}_i$$. Note that we are only displaying the first six elements through the head function. You can obtain the predicted values by calling the predict function on the fitted model. # store the predictions as predictg predictg <- predict(modg) head(predictg) ## 1 2 3 4 5 6 ## 70.51812 45.79862 51.65206 62.45556 45.27079 38.01784 This returns a vector with for, each case in the data, the predicted value $$\hat{Y}_{M,i}$$. You can use these variables to create e.g. a histogram of the errors: hist(errorg) and a predicted by residual plot # scatterplot of predicted vs residual plot(predictg, errorg, xlab = "predicted", ylab = "residual") # add a horizontal line (h=0 is for horizontal at 0, # and lty = 3 makes it a dotted line abline(h=0,lty=3) You can also call the plot function directly on the fitted model, which produces a range of plots to assess the model assumptions: plot(modg)    ## 4.5 Plotting pairwise scatterplots for many variables A final tip relates to exploring relations between many variables (e.g. potential predictors and dependent variables). While you can inspect pairwise relations between variables by creating a scatterplot for each pair of variables, this quickly becomes tedious. You can save yourself some work by using a function that produces a matrix of pairwise scatterplots directly. One option for this is to use the pairs function, and supply this with a selection of variables in a data.frame. For instance, in the data set we considered now, we might be interested in the relations between hate_groups_per_million, percent_bachelors_degree_or_higher, percent_in_poverty, and percent_Trump_votes. We can obtain a matrix of all pairwise scatterplots between these variables as follows (note that rather than typing the variable names, I’m selecting column 4 to 7, which correspond to these variables): pairs(dat[,4:7]) If you don’t like the look of these base R graphics and prefer ggplot2, you can use the ggpairs function from the GGally package to get a similar plot: library(GGally) ggpairs(dat[,4:7]) ## Registered S3 method overwritten by 'GGally': ## method from ## +.gg ggplot2 ## 4.6 Multicollinearity and outlier detection The car package provides useful functions to assess multicollinearity. In particular, it provides the vif function to compute the Variance Inflation Factor (VIF) for each predictor in the data. modg_vif <- car::vif(modg) modg_vif ## hate_groups_per_million percent_bachelors_degree_or_higher ## 1.093119 1.093119 To compute the tolerance, you can simply transform the results from this function, as follows: modg_tolerance <- 1/modg_vif modg_tolerance ## hate_groups_per_million percent_bachelors_degree_or_higher ## 0.9148138 0.9148138 There are a large number of measures to detect potential outliers. You can get many of these with the influence.measures function, which is provided in the (base R) stats package. Let’s try this with the full data set (including the District of Columbia): modg <- lm(percent_Trump_votes ~ hate_groups_per_million + percent_bachelors_degree_or_higher, data=trump2016) influence.measures(modg) ## Influence measures of ## lm(formula = percent_Trump_votes ~ hate_groups_per_million + percent_bachelors_degree_or_higher, data = trump2016) : ## ## dfb.1_ dfb.h___ dfb.p___ dffit cov.r cook.d hat inf ## 1 -0.52688 -0.296032 0.521272 -0.56266 1.159 1.04e-01 0.1676 ## 2 0.00392 -0.061502 0.020901 0.09322 1.087 2.94e-03 0.0349 ## 3 -0.03341 0.004670 0.019253 -0.06573 1.077 1.46e-03 0.0225 ## 4 -0.03771 -0.023320 0.035989 -0.04341 1.148 6.41e-04 0.0734 ## 5 0.06591 0.148803 -0.142949 -0.32192 0.876 3.27e-02 0.0277 ## 6 -0.24979 -0.153330 0.304489 0.36014 1.029 4.26e-02 0.0705 ## 7 -0.11843 -0.105623 0.150998 0.18404 1.122 1.14e-02 0.0753 ## 8 -0.01473 -0.013061 -0.007111 -0.12198 1.038 4.99e-03 0.0201 ## 9 2.52447 -5.302567 -1.681047 -6.87659 4.759 1.38e+01 0.8587 * ## 10 -0.02247 0.000377 0.011937 -0.05068 1.080 8.72e-04 0.0211 ## 11 0.00853 -0.004034 0.000226 0.03959 1.081 5.33e-04 0.0198 ## 12 0.08150 0.367500 -0.215915 -0.52466 0.747 8.21e-02 0.0399 * ## 13 0.08875 0.096324 -0.086731 0.13557 1.106 6.22e-03 0.0559 ## 14 0.03414 0.051211 -0.063462 -0.12988 1.054 5.67e-03 0.0274 ## 15 0.00905 0.003813 -0.007741 0.01140 1.105 4.42e-05 0.0366 ## 16 -0.02482 0.014259 0.013319 -0.04802 1.089 7.84e-04 0.0273 ## 17 -0.02606 -0.087778 0.083161 0.23956 0.943 1.86e-02 0.0239 ## 18 0.09668 0.060449 -0.090373 0.11583 1.114 4.55e-03 0.0571 ## 19 -0.03092 -0.008024 0.026492 -0.03570 1.113 4.34e-04 0.0445 ## 20 -0.00993 0.025266 -0.009797 -0.07984 1.069 2.16e-03 0.0218 ## 21 0.02121 0.012855 -0.026006 -0.03119 1.139 3.31e-04 0.0656 ## 22 -0.05632 -0.040191 0.067534 0.07593 1.194 1.96e-03 0.1105 * ## 23 -0.05253 0.002615 0.031027 -0.10310 1.058 3.58e-03 0.0222 ## 24 -0.04313 -0.051157 0.063607 0.09606 1.095 3.13e-03 0.0408 ## 25 -0.19099 -0.129701 0.186786 -0.22017 1.139 1.63e-02 0.0926 ## 26 0.05673 0.023999 -0.040637 0.10148 1.062 3.47e-03 0.0235 ## 27 0.08441 0.250403 -0.093250 0.30080 1.047 3.00e-02 0.0642 ## 28 0.03238 -0.057781 0.025177 0.24179 0.917 1.88e-02 0.0208 ## 29 -0.31423 0.029236 0.242506 -0.39419 0.882 4.90e-02 0.0399 ## 30 -0.08398 -0.019730 0.109755 0.17291 1.046 1.00e-02 0.0344 ## 31 -0.09407 -0.083653 0.121603 0.15189 1.116 7.80e-03 0.0652 ## 32 -0.19154 0.123269 0.103240 -0.36583 0.836 4.16e-02 0.0292 ## 33 0.05688 0.055368 -0.081363 -0.12081 1.083 4.93e-03 0.0386 ## 34 0.00256 -0.000673 -0.000647 0.00874 1.087 2.60e-05 0.0200 ## 35 0.06753 -0.143108 0.016610 0.32284 0.852 3.27e-02 0.0251 ## 36 -0.02617 -0.003339 0.018595 -0.04122 1.088 5.78e-04 0.0250 ## 37 0.16554 -0.022263 -0.122110 0.22264 1.011 1.64e-02 0.0344 ## 38 0.01776 0.035477 -0.042254 -0.10704 1.060 3.86e-03 0.0242 ## 39 -0.00413 0.001328 0.000514 -0.01652 1.086 9.28e-05 0.0198 ## 40 0.04014 0.090825 -0.075753 -0.14660 1.067 7.23e-03 0.0367 ## 41 0.01379 -0.001198 -0.009068 0.02285 1.091 1.78e-04 0.0249 ## 42 0.16164 0.235335 -0.162909 0.30237 1.030 3.02e-02 0.0581 ## 43 0.11823 0.095192 -0.108844 0.16490 1.072 9.14e-03 0.0433 ## 44 0.00868 -0.006344 -0.002861 0.02384 1.088 1.93e-04 0.0227 ## 45 0.00224 0.007721 -0.005479 -0.01283 1.101 5.61e-05 0.0327 ## 46 0.13369 0.127883 -0.176909 -0.22824 1.075 1.74e-02 0.0595 ## 47 -0.10655 -0.025968 0.131619 0.18477 1.059 1.14e-02 0.0423 ## 48 0.04786 0.044087 -0.072617 -0.12127 1.068 4.96e-03 0.0314 ## 49 0.16158 0.033660 -0.144034 0.17103 1.125 9.88e-03 0.0745 ## 50 -0.02618 0.027968 0.006136 -0.07926 1.074 2.13e-03 0.0240 ## 51 0.27179 0.076981 -0.211548 0.38638 0.801 4.58e-02 0.0280 * You can see that this provides a quite a few measures for each case (i.e. state) in the data! The first three are so-called DFBETAS measures, which reflect the standardized difference in the estimated parameters (intercept and slopes of hate_groups_per_million and percent_bachelors_degree_or_higher, respectively) that result from deleting that particular case from the data. The dffit column refers to the DFFITS measure shows the difference in the standardized predicted value for that case, after removing the case for the estimation of the model. The value in the cov.r column is the covariance ratio measure, which assesses the influence of a case on multicollinearity. Then the Cook’s distance is provided in the cook.d column, and the hat column provides the leverage values. Finally, the inf column flags potential outliers according to any of these measures. I would not advice you to blindly delete the flagged cases. These are cases which may be outliers. Personally, I use the Cook’s distance more than the other measures. You can obtain just the Cook’s distances with the cooks.distance function: modg_cooks_distance <- cooks.distance(modg) # get a quick summary of the values summary(modg_cooks_distance) ## Min. 1st Qu. Median Mean 3rd Qu. Max. ## 0.000026 0.001169 0.004989 0.284643 0.018019 13.810613 The summary shows that there is at least one case with a Cook’s distance larger than 1. We can see which states have a large Cook’s distance as follows: trump2016$state[which(modg_cooks_distance > 1)]
##  "District of Columbia"

which indicates that the District of Columbia is likely an outlier.

### References

Fox, John, Sanford Weisberg, and Brad Price. 2021. Car: Companion to Applied Regression. https://CRAN.R-project.org/package=car.
Schloerke, Barret, Di Cook, Joseph Larmarange, Francois Briatte, Moritz Marbach, Edwin Thoen, Amos Elberg, and Jason Crowley. 2021. GGally: Extension to Ggplot2. https://CRAN.R-project.org/package=GGally.