# 6 Basic Regression

Now that we are equipped with data visualization skills from Chapter 3, an understanding of the “tidy” data format from Chapter 4, and data wrangling skills from Chapter 5, we now proceed with data modeling. The fundamental premise of data modeling is *to make explicit the relationship* between:

- an outcome variable \(y\), also called a dependent variable and
- an explanatory/predictor variable \(x\), also called an independent variable or covariate.

Another way to state this is using mathematical terminology: we will model the outcome variable \(y\) *as a function* of the explanatory/predictor variable \(x\). Why do we have two different labels, explanatory and predictor, for the variable \(x\)? That’s because roughly speaking data modeling can be used for two purposes:

**Modeling for prediction**: You want to predict an outcome variable \(y\) based on the information contained in a set of predictor variables. You don’t care so much about understanding how all the variables relate and interact, but so long as you can make good predictions about \(y\), you’re fine. For example, if we know many individuals’ risk factors for lung cancer, such as smoking habits and age, can we predict whether or not they will develop lung cancer? Here we wouldn’t care so much about distinguishing the degree to which the different risk factors contribute to lung cancer, but instead only on whether or not they could be put together to make reliable predictions.**Modeling for explanation**: You want to explicitly describe the relationship between an outcome variable \(y\) and a set of explanatory variables, determine the significance of any found relationships, and have measures summarizing these. Continuing our example from above, we would now be interested in describing the individual effects of the different risk factors and quantifying the magnitude of these effects. One reason could be to design an intervention to reduce lung cancer cases in a population, such as targeting smokers of a specific age group with an advertisement for smoking cessation programs. In this book, we’ll focus more on this latter purpose.

Data modeling is used in a wide variety of fields, including statistical inference, causal inference, artificial intelligence, and machine learning. There are many techniques for data modeling, such as tree-based models, neural networks and deep learning, and supervised learning. In this chapter, we’ll focus on one particular technique: *linear regression*, one of the most commonly-used and easy-to-understand approaches to modeling. Recall our discussion in Subsection 2.4.3 on numerical and categorical variables. Linear regression involves:

- an outcome variable \(y\) that is
*numerical*and - explanatory variables \(\vec{x}\) that are either
*numerical*or*categorical*.

With linear regression there is always only one numerical outcome variable \(y\) but we have choices on both the number and the type of explanatory variables \(\vec{x}\) to use. We’re going to cover the following regression scenarios:

- In this current chapter on basic regression, we’ll always have only one explanatory variable.
- In the next chapter, Chapter 7 on
*multiple regression*, we’ll have more than one explanatory variable:- We’ll focus on two numerical explanatory variables \(x_1\) and \(x_2\) in Section 7.1. This can be denoted as \(\vec{x}\) as well since we have more than one explanatory variable.
- We’ll use one numerical and one categorical explanatory variable in Section 7.1. We’ll also introduce
*interaction models*here; there, the effect of one explanatory variable depends on the value of another.

We’ll study all four of these regression scenarios using real data, all easily accessible via R packages!

### Needed packages

In this chapter we introduce a new package, `moderndive`

, that is an accompaniment package to this ModernDive book. It includes useful functions for linear regression and other functions as well as data used later in the book. Let’s now load all the packages needed for this chapter. If needed, read Section 2.3 for information on how to install and load R packages.

```
library(ggplot2)
library(dplyr)
library(moderndive)
library(gapminder)
library(skimr)
```

### DataCamp

The introductory basic regression analysis below was the inspiration for a large part of ModernDive co-author Albert Y. Kim’s DataCamp course “Modeling with Data in the Tidyverse.” If you’re interested in complementing your learning below in an interactive online environment, click on the image below to access the course. The relevant chapters are Chapter 1 “Introduction to Modeling” and Chapter 2 “Modeling with Basic Regression”.

## 6.1 One numerical explanatory variable

Why do some professors and instructors at universities and colleges get high teaching evaluations from students while others don’t? What factors can explain these differences? Are there biases? These are questions that are of interest to university/college administrators, as teaching evaluations are among the many criteria considered in determining which professors and instructors should get promotions. Researchers at the University of Texas in Austin, Texas (UT Austin) tried to answer this question: what factors can explain differences in instructor’s teaching evaluation scores? To this end, they collected information on \(n = 463\) instructors. A full description of the study can be found at openintro.org.

We’ll keep things simple for now and try to explain differences in instructor evaluation scores as a function of one numerical variable: their “beauty score.” The specifics on how this score was calculated will be described shortly.

Could it be that instructors with higher beauty scores also have higher teaching evaluations? Could it be instead that instructors with higher beauty scores tend to have lower teaching evaluations? Or could it be there is no relationship between beauty score and teaching evaluations?

We’ll achieve ways to address these questions by modeling the relationship between these two variables with a particular kind of linear regression called *simple linear regression*. Simple linear regression is the most basic form of linear regression. With it we have

- A numerical outcome variable \(y\). In this case, their teaching score.
- A single numerical explanatory variable \(x\). In this case, their beauty score.

### 6.1.1 Exploratory data analysis

A crucial step before doing any kind of modeling or analysis is performing an *exploratory data analysis*, or EDA, of all our data. Exploratory data analysis can give you a sense of the distribution of the data, and whether there are outliers and/or missing values. Most importantly, it can inform how to build your model. There are many approaches to exploratory data analysis; here are three:

- Most fundamentally: just looking at the raw values, in a spreadsheet for example. While this may seem trivial, many people ignore this crucial step!
- Computing summary statistics likes means, medians, and standard deviations.
- Creating data visualizations.

Let’s load the data, `select`

only a subset of the variables, and look at the raw values. Recall you can look at the raw values by running `View()`

in the console in RStudio to pop-up the spreadsheet viewer with the data frame of interest as the argument to `View()`

. Here, however, we present only a snapshot of five randomly chosen rows:

```
evals_ch6 <- evals %>%
select(score, bty_avg, age)
```

```
evals_ch6 %>%
sample_n(5)
```

score | bty_avg | age |
---|---|---|

3.6 | 6.67 | 34 |

4.9 | 3.50 | 43 |

3.3 | 2.33 | 47 |

4.4 | 4.67 | 33 |

4.7 | 3.67 | 60 |

While a full description of each of these variables can be found at openintro.org, let’s summarize what each of these variables represents.

`score`

: Numerical variable of the average teaching score based on students’ evaluations between 1 and 5. This is the outcome variable \(y\) of interest.`bty_avg`

: Numerical variable of average “beauty” rating based on a panel of 6 students’ scores between 1 and 10. This is the numerical explanatory variable \(x\) of interest. Here 1 corresponds to a low beauty rating and 10 to a high beauty rating.`age`

: A numerical variable of age in years as an integer value.

Another way to look at the raw values is using the `glimpse()`

function, which gives us a slightly different view of the data. We see `Observations: 463`

, indicating that there are 463 observations in `evals`

, each corresponding to a particular instructor at UT Austin. Expressed differently, each row in the data frame `evals`

corresponds to one of 463 instructors.

`glimpse(evals_ch6)`

```
Observations: 463
Variables: 3
$ score <dbl> 4.7, 4.1, 3.9, 4.8, 4.6, 4.3, 2.8, 4.1, 3.4, 4.5, 3.8, 4.5, 4…
$ bty_avg <dbl> 5.00, 5.00, 5.00, 5.00, 3.00, 3.00, 3.00, 3.33, 3.33, 3.17, 3…
$ age <int> 36, 36, 36, 36, 59, 59, 59, 51, 51, 40, 40, 40, 40, 40, 40, 4…
```

Since both the outcome variable `score`

and the explanatory variable `bty_avg`

are numerical, we can compute summary statistics about them such as the mean, median, and standard deviation. Let’s take `evals_ch6`

and select only the two variables of interest for now. However, let’s instead pipe this into the `skim()`

function from the `skimr`

package. This function quickly uses a “skim” of the data to return the following summary information about each variable.

```
evals_ch6 %>%
select(score, bty_avg) %>%
skim()
```

```
Skim summary statistics
n obs: 463
n variables: 2
── Variable type:numeric ─────────────────────────────────────────────────────
variable missing complete n mean sd p0 p25 p50 p75 p100 hist
bty_avg 0 463 463 4.42 1.53 1.67 3.17 4.33 5.5 8.17 ▂▅▅▇▃▃▂▁
score 0 463 463 4.17 0.54 2.3 3.8 4.3 4.6 5 ▁▁▂▃▅▇▇▆
```

In this case for our two numerical variables `bty_avg`

beauty score and teaching score `score`

it returns:

`missing`

: the number of missing values`complete`

: the number of non-missing or complete values`n`

: the total number of values`mean`

: the average`sd`

: the standard deviation`p0`

: the 0^{th}percentile: the value at which 0% of observations are smaller than it. This is also known as the*minimum*`p25`

: the 25^{th}percentile: the value at which 25% of observations are smaller than it. This is also known as the*1*^{st}quartile`p50`

: the 25^{th}percentile: the value at which 50% of observations are smaller than it. This is also know as the*2*quartile and more commonly the^{nd}*median*`p75`

: the 75^{th}percentile: the value at which 75% of observations are smaller than it. This is also known as the*3*^{rd}quartile`p100`

: the 100^{th}percentile: the value at which 100% of observations are smaller than it. This is also known as the*maximum*- A quick snapshot of the
`hist`

ogram

We get an idea of how the values in both variables are distributed. For example, the mean teaching score was 4.17 out of 5 whereas the mean beauty score was 4.42 out of 10. Furthermore, the middle 50% of teaching scores were between 3.80 and 4.6 (the first and third quartiles) while the middle 50% of beauty scores were between 3.17 and 5.5 out of 10.

The `skim()`

function however only returns what are called *univariate* summaries, i.e. summaries about single variables at a time. Since we are considering the relationship between two numerical variables, it would be nice to have a summary statistic that simultaneously considers both variables. The *correlation coefficient* is a *bivariate* summary statistic that fits this bill. *Coefficients* in general are quantitative expressions of a specific property of a phenomenon. A correlation coefficient is a quantitative expression between -1 and 1 that summarizes the *strength of the linear relationship between two numerical variables*:

- -1 indicates a perfect
*negative relationship*: as the value of one variable goes up, the value of the other variable tends to go down. - 0 indicates no relationship: the values of both variables go up/down independently of each other.
- +1 indicates a perfect
*positive relationship*: as the value of one variable goes up, the value of the other variable tends to go up as well.

Figure 6.1 gives examples of different correlation coefficient values for hypothetical numerical variables \(x\) and \(y\). We see that while for a correlation coefficient of -0.75 there is still a negative relationship between \(x\) and \(y\), it is not as strong as the negative relationship between \(x\) and \(y\) when the correlation coefficient is -1.

The correlation coefficient is computed using the `get_correlation()`

function in the `moderndive`

package, where in this case the inputs to the function are the two numerical variables from which we want to calculate the correlation coefficient. We place the name of the response variable on the left hand side of the `~`

and the explanatory variable on the right hand side of the “tilde.” We will use this same “formula” syntax with regression later in this chapter.

```
evals_ch6 %>%
get_correlation(formula = score ~ bty_avg)
```

```
# A tibble: 1 x 1
correlation
<dbl>
1 0.187
```

The correlation coefficient can also be computed using the `cor()`

function, where in this case the inputs to the function are the two numerical variables from which we want to calculate the correlation coefficient. Recall from Subsection 2.4.3 that the `$`

pulls out specific variables from a data frame:

`cor(x = evals_ch6$bty_avg, y = evals_ch6$score)`

`[1] 0.187`

In our case, the correlation coefficient of 0.187 indicates that the relationship between teaching evaluation score and beauty average is “weakly positive.” There is a certain amount of subjectivity in interpreting correlation coefficients, especially those that aren’t close to -1, 0, and 1. For help developing such intuition and more discussion on the correlation coefficient see Subsection 6.3.1 below.

Let’s now proceed by visualizing this data. Since both the `score`

and `bty_avg`

variables are numerical, a scatterplot is an appropriate graph to visualize this data. Let’s do this using `geom_point()`

and set informative axes labels and title and display the result in Figure 6.2.

```
ggplot(evals_ch6, aes(x = bty_avg, y = score)) +
geom_point() +
labs(x = "Beauty Score", y = "Teaching Score",
title = "Relationship of teaching and beauty scores")
```

Observe the following:

- Most “beauty” scores lie between 2 and 8.
- Most teaching scores lie between 3 and 5.
- Recall our earlier computation of the correlation coefficient, which describes the strength of the linear relationship between two numerical variables. Looking at Figure 6.3, it is not immediately apparent that these two variables are positively related. This is to be expected given the positive, but rather weak (close to 0), correlation coefficient of 0.187.

Before we continue, we bring to light an important fact about this dataset: it suffers from *overplotting*. Recall from the data visualization Subsection 3.3.2 that overplotting occurs when several points are stacked directly on top of each other thereby obscuring the number of points. For example, let’s focus on the 6 points in the top-right of the plot with a beauty score of around 8 out of 10: are there truly only 6 points, or are there many more just stacked on top of each other? You can think of these as *ties*. Let’s break up these ties with a little random “jitter” added to the points in Figure 6.3.

Jittering adds a little random bump to each of the points to break up these ties: just enough so you can distinguish them, but not so much that the plot is overly altered. Furthermore, jittering is strictly a visualization tool; it does not alter the original values in the dataset.

Let’s compare side-by-side the regular scatterplot in Figure 6.2 with the jittered scatterplot in Figure 6.3 in Figure 6.4.

We make several further observations:

- Focusing our attention on the top-right of the plot again, as noted earlier where there seemed to only be 6 points in the regular scatterplot, we see there were in fact really 9 as seen in the jittered scatterplot.
- A further interesting trend is that the jittering revealed a large number of instructors with beauty scores of between 3 and 4.5, towards the lower end of the beauty scale.

Going forward for simplicity’s sake however, we’ll only present regular scatterplot rather than the jittered scatterplots; we’ll only keep the overplotting in mind whenever looking at such plots. Going back to scatterplot in Figure 6.2, let’s improve on it by adding a “regression line” in Figure 6.5. This is easily done by adding a new layer to the `ggplot`

code that created Figure 6.3: `+ geom_smooth(method = "lm")`

. A regression line is a “best fitting” line in that of all possible lines you could draw on this plot, it is “best” in terms of some mathematical criteria. We discuss the criteria for “best” in Subsection 6.3.3 below, but we suggest you read this only after covering the concept of a *residual* coming up in Subsection 6.1.3.

```
ggplot(evals_ch6, aes(x = bty_avg, y = score)) +
geom_point() +
labs(x = "Beauty Score", y = "Teaching Score",
title = "Relationship of teaching and beauty scores") +
geom_smooth(method = "lm")
```

When viewed on this plot, the regression line is a visual summary of the relationship between two numerical variables, in our case the outcome variable `score`

and the explanatory variable `bty_avg`

. The positive slope of the blue line is consistent with our observed correlation coefficient of 0.187 suggesting that there is a positive relationship between `score`

and `bty_avg`

. We’ll see later however that while the correlation coefficient is not equal to the slope of this line, they always have the same sign: positive or negative.

What are the grey bands surrounding the blue line? These are *standard error* bands, which can be thought of as error/uncertainty bands. Let’s skip this idea for now and suppress these grey bars for now by adding the argument `se = FALSE`

to `geom_smooth(method = "lm")`

. We’ll introduce standard errors in Chapter 8 on sampling, use them for constructing *confidence intervals* and conducting *hypothesis tests* in Chapters 9 and 10, and consider them when we revisit regression in Chapter 11.

```
ggplot(evals_ch6, aes(x = bty_avg, y = score)) +
geom_point() +
labs(x = "Beauty Score", y = "Teaching Score",
title = "Relationship of teaching and beauty scores") +
geom_smooth(method = "lm", se = FALSE)
```

*Learning check*

**(LC6.1)** Conduct a new exploratory data analysis with the same outcome variable \(y\) being `score`

but with `age`

as the new explanatory variable \(x\). Remember, this involves three things:

- Looking at the raw values.
- Computing summary statistics of the variables of interest.
- Creating informative visualizations.

What can you say about the relationship between age and teaching scores based on this exploration?

### 6.1.2 Simple linear regression

You may recall from secondary school / high school algebra, in general, the equation of a line is \(y = a + bx\), which is defined by two coefficients. Recall we defined this earlier as “quantitative expressions of a specific property of a phenomenon.” These two coefficients are:

- the intercept coefficient \(a\), or the value of \(y\) when \(x = 0\), and
- the slope coefficient \(b\), or the increase in \(y\) for every increase of one in \(x\).

However, when defining a line specifically for regression, like the blue regression line in Figure 6.6, we use slightly different notation: the equation of the regression line is \(\widehat{y} = b_0 + b_1 \cdot x\) where

- the intercept coefficient is \(b_0\), or the value of \(\widehat{y}\) when \(x=0\), and
- the slope coefficient \(b_1\), or the increase in \(\widehat{y}\) for every increase of one in \(x\).

Why do we put a “hat” on top of the \(y\)? It’s a form of notation commonly used in regression, which we’ll introduce in the next Subsection 6.1.3 when we discuss *fitted values*. For now, let’s ignore the hat and treat the equation of the line as you would from secondary school / high school algebra recognizing the slope and the intercept. We know looking at Figure 6.6 that the slope coefficient corresponding to `bty_avg`

should be positive. Why? Because as `bty_avg`

increases, professors tend to roughly have larger teaching evaluation `scores`

. However, what are the specific values of the intercept and slope coefficients? Let’s not worry about computing these by hand, but instead let the computer do the work for us. Specifically let’s use R!

Let’s get the value of the intercept and slope coefficients by outputting something called the *linear regression table*. We will fit the linear regression model to the `data`

using the `lm()`

function and save this to `score_model`

. `lm`

stands for “linear model”, given that we are dealing with lines. When we say “fit”, we are saying find the best fitting line to this data.

The `lm()`

function that “fits” the linear regression model is typically used as `lm(y ~ x, data = data_frame_name)`

where:

`y`

is the outcome variable, followed by a tilde (`~`

). This is likely the key to the left of “1” on your keyboard. In our case,`y`

is set to`score`

.`x`

is the explanatory variable. In our case,`x`

is set to`bty_avg`

. We call the combination`y ~ x`

a*model formula*. Recall the use of this notation when we computed the correlation coefficient using the`get_correlation()`

function in Subsection 6.1.1.`data_frame_name`

is the name of the data frame that contains the variables`y`

and`x`

. In our case,`data_frame_name`

is the`evals_ch6`

data frame.

```
score_model <- lm(score ~ bty_avg, data = evals_ch6)
score_model
```

```
Call:
lm(formula = score ~ bty_avg, data = evals_ch6)
Coefficients:
(Intercept) bty_avg
3.8803 0.0666
```

This output is telling us that the `Intercept`

coefficient \(b_0\) of the regression line is 3.8803 and the slope coefficient for `by_avg`

is 0.0666. Therefore the blue regression line in Figure 6.6 is

\[\widehat{\text{score}} = b_0 + b_{\text{bty_avg}} \cdot\text{bty_avg} = 3.8803 + 0.0666\cdot\text{ bty_avg}\]

where

- The intercept coefficient \(b_0 = 3.8803\) means for instructors that had a hypothetical beauty score of 0, we would expect them to have on average a teaching score of 3.8803. In this case however, while the intercept has a mathematical interpretation when defining the regression line, there is no
*practical*interpretation since`score`

is an average of a panel of 6 students’ ratings from 1 to 10, a`bty_avg`

of 0 would be impossible. Furthermore, no instructors had a beauty score anywhere near 0 in this data. Of more interest is the slope coefficient associated with

`bty_avg`

: \(b_{\text{bty avg}} = +0.0666\). This is a numerical quantity that summarizes the relationship between the outcome and explanatory variables. Note that the sign is positive, suggesting a positive relationship between beauty scores and teaching scores, meaning as beauty scores go up, so also do teaching scores go up. The slope’s precise interpretation is:For every increase of 1 unit in

`bty_avg`

, there is an*associated*increase of,*on average*, 0.0666 units of`score`

.

Such interpretations need be carefully worded:

- We only stated that there is an
*associated*increase, and not necessarily a*causal*increase. For example, perhaps it’s not that beauty directly affects teaching scores, but instead individuals from wealthier backgrounds tend to have had better education and training, and hence have higher teaching scores, but these same individuals also have higher beauty scores. Avoiding such reasoning can be summarized by the adage “correlation is not necessarily causation.” In other words, just because two variables are correlated, it doesn’t mean one directly causes the other. We discuss these ideas more in Subsection 6.3.2.

- We say that this associated increase is
*on average*0.0666 units of teaching`score`

and not that the associated increase is*exactly*0.0666 units of`score`

across all values of`bty_avg`

. This is because the slope is the average increase across all points as shown by the regression line in Figure 6.6.

Now that we’ve learned how to compute the equation for the blue regression line in Figure 6.6 and interpreted all its terms, let’s take our modeling one step further. This time after fitting the model using the `lm()`

, let’s get something called the *regression table* using the `get_regression_table()`

function from the `moderndive`

package:

```
# Fit regression model:
score_model <- lm(score ~ bty_avg, data = evals_ch6)
# Get regression table:
get_regression_table(score_model)
```

term | estimate | std_error | statistic | p_value | lower_ci | upper_ci |
---|---|---|---|---|---|---|

intercept | 3.880 | 0.076 | 50.96 | 0 | 3.731 | 4.030 |

bty_avg | 0.067 | 0.016 | 4.09 | 0 | 0.035 | 0.099 |

Note how we took the output of the model fit saved in `score_model`

and used it as an input to the subsequent `get_regression_table()`

function. The output now looks like a table: in fact it is a data frame. The values of the intercept and slope of 3.880 and 0.0666 are now in the `estimate`

column. But what are the remaining 5 columns: `std_error`

, `statistic`

, `p_value`

, `lower_ci`

and `upper_ci`

? What do they tell us? They tell us about both the *statistical significance* and *practical significance* of our model results. You can think of this loosely as the “meaningfulness” of the results from a statistical perspective.

We are going to put aside these ideas for now and revisit them in Chapter 11 on (statistical) inference for regression, after we’ve had a chance to cover:

- Standard errors in Chapter 8 (
`std_error`

) - Confidence intervals in Chapter 9 (
`lower_ci`

and`upper_ci`

) - Hypothesis testing in Chapter 10 (
`statistic`

and`p_value`

).

For now, we’ll only focus on the `term`

and `estimate`

columns of any regression table.

The `get_regression_table()`

from the `moderndive`

is an example of what’s known as a *wrapper function* in computer programming, which takes other pre-existing functions and “wraps” them into a single function. This concept is illustrated in Figure 6.7.

So all you need to worry about is the what the inputs look like and what the outputs look like; you leave all the other details “under the hood of the car.” In our regression modeling example, the `get_regression_table()`

has

- Input: A saved
`lm()`

linear regression - Output: A data frame with information on the intercept and slope of the regression line.

If you’re interested in learning more about the `get_regression_table()`

function’s construction and thinking, see Subsection 6.3.4 below.

*Learning check*

**(LC6.2)** Fit a new simple linear regression using `lm(score ~ age, data = evals_ch6)`

where `age`

is the new explanatory variable \(x\). Get information about the “best-fitting” line from the regression table by applying the `get_regression_table()`

function. How do the regression results match up with the results from your exploratory data analysis above?

### 6.1.3 Observed/fitted values and residuals

We just saw how to get the value of the intercept and the slope of the regression line from the regression table generated by `get_regression_table()`

. Now instead, say we want information on individual points. In this case, we focus on one of the \(n = 463\) instructors in this dataset, corresponding to a single row of `evals_ch6`

.

For example, say we are interested in the 21st instructor in this dataset:

score | bty_avg | age |
---|---|---|

4.9 | 7.33 | 31 |

What is the value on the blue line corresponding to this instructor’s `bty_avg`

of 7.333? In Figure 6.8 we mark three values in particular corresponding to this instructor.

- Red circle: This is the
*observed value*\(y\) = 4.9 and corresponds to this instructor’s actual teaching score. - Red square: This is the
*fitted value*\(\widehat{y}\) and corresponds to the value on the regression line for \(x\) = 7.333. This value is computed using the intercept and slope in the regression table above: \[\widehat{y} = b_0 + b_1 \cdot x = 3.88 + 0.067 * 7.333 = 4.369\] - Blue arrow: The length of this arrow is the
*residual*and is computed by subtracting the fitted value \(\widehat{y}\) from the observed value \(y\). The residual can be thought of as the error or “lack of fit” of the regression line. In the case of this instructor, it is \(y - \widehat{y}\) = 4.9 - 4.369 = 0.531. In other words, the model was off by 0.531 teaching score units for this instructor.

What if we want both

- the fitted value \(\widehat{y} = b_0 + b_1 \cdot x\) and
- the residual \(y - \widehat{y}\)

not only the 21st instructor but for all 463 instructors in the study? Recall that each instructor corresponds to one of the 463 rows in the `evals_ch6`

data frame and also one of the 463 points in the regression plot in Figure 6.6.

We could repeat the above calculations by hand 463 times, but that would be tedious and time consuming. Instead, let’s use the `get_regression_points()`

function that we’ve included in the `moderndive`

R package. Note that in the table below we only present the results for the 21st through the 24th instructors.

```
regression_points <- get_regression_points(score_model)
regression_points
```

ID | score | bty_avg | score_hat | residual |
---|---|---|---|---|

21 | 4.9 | 7.33 | 4.37 | 0.531 |

22 | 4.6 | 7.33 | 4.37 | 0.231 |

23 | 4.5 | 7.33 | 4.37 | 0.131 |

24 | 4.4 | 5.50 | 4.25 | 0.153 |

Just as with the `get_regression_table()`

function, the inputs to the `get_regression_points()`

function are the same, however the outputs are different. Let’s inspect the individual columns:

- The
`score`

column represents the observed value of the outcome variable \(y\). - The
`bty_avg`

column represents the values of the explanatory variable \(x\). - The
`score_hat`

column represents the fitted values \(\widehat{y}\). - The
`residual`

column represents the residuals \(y - \widehat{y}\).

`get_regression_points()`

is another example of a wrapper function we described in Figure 6.7. If you’re curious about this function as well, check out Subsection 6.3.4.

Just as we did for the 21st instructor in the `evals_ch6`

dataset (in the first row of the table above), let’s repeat the above calculations for the 24th instructor in the `evals_ch6`

dataset (in the fourth row of the table above):

`score`

= 4.4 is the observed value \(y\) for this instructor.`bty_avg`

= 5.50 is the value of the explanatory variable \(x\) for this instructor.`score_hat`

= 4.25 = 3.88 + 0.067 * \(x\) = 3.88 + 0.067 * 5.50 is the fitted value \(\widehat{y}\) for this instructor.`residual`

= 0.153 = 4.4 - 4.25 is the value of the residual for this instructor. In other words, the model was off by 0.153 teaching score units for this instructor.

More development of this idea appears in Section 6.3.3 and we encourage you to read that section after you investigate residuals.

### 6.1.4 Residual analysis

Recall the residuals can be thought of as the error or the “lack-of-fit” between the observed value \(y\) and the fitted value \(\widehat{y}\) on the blue regression line in Figure 6.6. Ideally when we fit a regression model, we’d like there to be *no systematic pattern* to these residuals. We’ll be more specific as to what we mean by *no systematic pattern* when we see Figure 6.10 below, but let’s keep this notion imprecise for now. Investigating any such patterns is known as *residual analysis* and is the theme of this section.

We’ll perform our residual analysis in two ways:

- Creating a scatterplot with the residuals on the \(y\)-axis and the original explanatory variable \(x\) on the \(x\)-axis.
- Creating a histogram of the residuals, thereby showing the
*distribution*of the residuals.

First, recall in Figure 6.8 above we created a scatterplot where

- on the vertical axis we had the teaching score \(y\),
- on the horizontal axis we had the beauty score \(x\), and
- the blue arrow represented the residual for one particular instructor.

Instead, in Figure 6.9 below, let’s create a scatterplot where

- On the vertical axis we have the residual \(y-\widehat{y}\) instead
- On the horizontal axis we have the beauty score \(x\) as before:

```
ggplot(regression_points, aes(x = bty_avg, y = residual)) +
geom_point() +
labs(x = "Beauty Score", y = "Residual") +
geom_hline(yintercept = 0, col = "blue", size = 1)
```

You can think of Figure 6.9 as Figure 6.8 but with the blue line flattened out to \(y=0\). Does it seem like there is *no systematic pattern* to the residuals? This question is rather qualitative and subjective in nature, thus different people may respond with different answers to the above question. However, it can be argued that there isn’t a *drastic* pattern in the residuals.

Let’s now get a little more precise in our definition of *no systematic pattern* in the residuals. Ideally, the residuals should behave *randomly*. In addition,

- the residuals should be on average 0. In other words, sometimes the regression model will make a positive error in that \(y - \widehat{y} > 0\), sometimes the regression model will make a negative error in that \(y - \widehat{y} < 0\), but
*on average*the error is 0. - Further, the value and spread of the residuals should not depend on the value of \(x\).

In Figure 6.10 below, we display some hypothetical examples where there are *drastic* patterns to the residuals. In Example 1, the value of the residual seems to depend on \(x\): the residuals tend to be positive for small and large values of \(x\) in this range, whereas values of \(x\) more in the middle tend to have negative residuals. In Example 2, while the residuals seem to be on average 0 for each value of \(x\), the spread of the residuals varies for different values of \(x\); this situation is known as *heteroskedasticity*.

The second way to perform a residual analysis is to look at the histogram of the residuals:

```
ggplot(regression_points, aes(x = residual)) +
geom_histogram(binwidth = 0.25, color = "white") +
labs(x = "Residual")
```

This histogram seems to indicate that we have more positive residuals than negative. Since the residual \(y-\widehat{y}\) is positive when \(y > \widehat{y}\), it seems our fitted teaching score from the regression model tends to *underestimate* the true teaching score. This histogram has a slight *left-skew* in that there is a long tail on the left. Another way to say this is this data exhibits a *negative skew*. Is this a problem? Again, there is a certain amount of subjectivity in the response. In the authors’ opinion, while there is a slight skew/pattern to the residuals, it isn’t a large concern. On the other hand, others might disagree with our assessment. Here are examples of an ideal and less than ideal pattern to the residuals when viewed in a histogram:

In fact, we’ll see later on that we would like the residuals to be *normally distributed* with mean 0. In other words, be bell-shaped and centered at 0! While this requirement and residual analysis in general may seem to some of you as not being overly critical at this point, we’ll see later after when we cover *inference for regression* in Chapter 11 that for the last five columns of the regression table from earlier (`std error`

, `statistic`

, `p_value`

,`lower_ci`

, and `upper_ci`

) to have valid interpretations, the above three conditions should roughly hold.

*Learning check*

**(LC6.3)** Continuing with our regression using `age`

as the explanatory variable and teaching `score`

as the outcome variable, use the `get_regression_points()`

function to get the observed values, fitted values, and residuals for all 463 instructors. Perform a residual analysis and look for any systematic patterns in the residuals. Ideally, there should be little to no pattern.

## 6.2 One categorical explanatory variable

It’s an unfortunate truth that life expectancy is not the same across various countries in the world; there are a multitude of factors that are associated with how long people live. International development agencies are very interested in studying these differences in the hope of understanding where governments should allocate resources to address this problem. In this section, we’ll explore differences in life expectancy in two ways:

- Differences between continents: Are there significant differences in life expectancy, on average, between the five continents of the world: Africa, the Americas, Asia, Europe, and Oceania?
- Differences within continents: How does life expectancy vary within the world’s five continents? For example, is the spread of life expectancy among the countries of Africa larger than the spread of life expectancy among the countries of Asia?

To answer such questions, we’ll study the `gapminder`

dataset in the `gapminder`

package. Recall we mentioned this dataset in Subsection 3.1.2 when we first studied the “Grammar of Graphics” introduced in Figure 3.1. This dataset has international development statistics such as life expectancy, GDP per capita, and population by country (\(n\) = 142) for 5-year intervals between 1952 and 2007.

We’ll use this data for linear regression again, but note that our explanatory variable \(x\) is now categorical, and not numerical like when we covered simple linear regression in Section 6.1. More precisely, we have:

- A numerical outcome variable \(y\). In this case, life expectancy.
- A single categorical explanatory variable \(x\), In this case, the continent the country is part of.

When the explanatory variable \(x\) is categorical, the concept of a “best-fitting” line is a little different than the one we saw previously in Section 6.1 where the explanatory variable \(x\) was numerical. We’ll study these differences shortly in Subsection 6.2.2, but first we conduct our exploratory data analysis.

### 6.2.1 Exploratory data analysis

Let’s load the `gapminder`

data and `filter()`

for only observations in 2007. Next we `select()`

only the variables we’ll need along with `gdpPercap`

, which is each country’s gross domestic product per capita (GDP). GDP is a rough measure of that country’s economic performance. (This will be used for the upcoming Learning Check). Lastly, we save this in a data frame with name `gapminder2007`

:

```
library(gapminder)
gapminder2007 <- gapminder %>%
filter(year == 2007) %>%
select(country, continent, lifeExp, gdpPercap)
```

You should look at the raw data values both by bringing up RStudio’s spreadsheet viewer and the `glimpse()`

function. In Table 6.5 we only show 5 randomly selected countries out of 142:

`View(gapminder2007)`

country | continent | lifeExp | gdpPercap |
---|---|---|---|

Slovak Republic | Europe | 74.7 | 18678 |

Israel | Asia | 80.7 | 25523 |

Bulgaria | Europe | 73.0 | 10681 |

Tanzania | Africa | 52.5 | 1107 |

Myanmar | Asia | 62.1 | 944 |

`glimpse(gapminder2007)`

```
Observations: 142
Variables: 4
$ country <fct> Afghanistan, Albania, Algeria, Angola, Argentina, Australia…
$ continent <fct> Asia, Europe, Africa, Africa, Americas, Oceania, Europe, As…
$ lifeExp <dbl> 43.8, 76.4, 72.3, 42.7, 75.3, 81.2, 79.8, 75.6, 64.1, 79.4,…
$ gdpPercap <dbl> 975, 5937, 6223, 4797, 12779, 34435, 36126, 29796, 1391, 33…
```

We see that the variable `continent`

is indeed categorical, as it is encoded as `fct`

which stands for “factor.” This is R’s way of storing categorical variables. Let’s once again apply the `skim()`

function from the `skimr`

package to our two variables of interest: `continent`

and `lifeExp`

:

```
gapminder2007 %>%
select(continent, lifeExp) %>%
skim()
```

```
Skim summary statistics
n obs: 142
n variables: 2
── Variable type:factor ──────────────────────────────────────────────────────
variable missing complete n n_unique top_counts
continent 0 142 142 5 Afr: 52, Asi: 33, Eur: 30, Ame: 25
ordered
FALSE
── Variable type:numeric ─────────────────────────────────────────────────────
variable missing complete n mean sd p0 p25 p50 p75 p100
lifeExp 0 142 142 67.01 12.07 39.61 57.16 71.94 76.41 82.6
hist
▂▂▂▂▂▃▇▇
```

The output now reports summaries for categorical variables (the variable type: factor) separately from the numerical variables. For the categorical variable `continent`

it now reports:

`missing`

,`complete`

,`n`

as before which are the number of missing, complete, and total number of values.`n_unique`

: The unique number of levels to this variable, corresponding to Africa, Asia, Americas, Europe, and Oceania`top_counts`

: In this case the top four counts: Africa has 52 entries each corresponding to a country, Asia has 33, Europe has 30, and Americans has 25. Not displayed is Oceania with 2 countries`ordered`

: Reporting whether the variable is “ordinal.” In this case, it is not ordered.

Given that the global median life expectancy is 71.94, half of the world’s countries (71 countries) will have a life expectancy less than 71.94. Further, half will have a life expectancy greater than this value. The mean life expectancy of 67.01 is lower however. Why are these two values different? Let’s look at a histogram of `lifeExp`

in Figure 6.13 to see why.

We see that this data is left-skewed/negatively skewed: there are a few countries with very low life expectancies that are bringing down the mean life expectancy. However, the median is less sensitive to the effects of such outliers. Hence the median is greater than the mean in this case. Let’s proceed by comparing median and mean life expectancy between continents by adding a `group_by(continent)`

to the above code:

```
lifeExp_by_continent <- gapminder2007 %>%
group_by(continent) %>%
summarize(median = median(lifeExp), mean = mean(lifeExp))
```

continent | median | mean |
---|---|---|

Africa | 52.9 | 54.8 |

Americas | 72.9 | 73.6 |

Asia | 72.4 | 70.7 |

Europe | 78.6 | 77.6 |

Oceania | 80.7 | 80.7 |

We see now that there are differences in life expectancies between the continents. For example let’s focus on only medians. While the median life expectancy across all \(n = 142\) countries in 2007 was 71.935, the median life expectancy across the \(n =52\) countries in Africa was only 52.927.

Let’s create a corresponding visualization. One way to compare the life expectancies of countries in different continents would be via a faceted histogram. Recall we saw back in the Data Visualization chapter, specifically Section 3.6, that facets allow us to split a visualization by the different levels of a categorical variable or factor variable. In Figure 6.14, the variable we facet by is `continent`

, which is categorical with five levels, each corresponding to the five continents of the world.

```
ggplot(gapminder2007, aes(x = lifeExp)) +
geom_histogram(binwidth = 5, color = "white") +
labs(x = "Life expectancy", y = "Number of countries",
title = "Life expectancy by continent") +
facet_wrap(~ continent, nrow = 2)
```

Another way would be via a `geom_boxplot`

where we map the categorical variable `continent`

to the \(x\)-axis and the different life expectancies within each continent on the \(y\)-axis; we do this in Figure 6.15.

```
ggplot(gapminder2007, aes(x = continent, y = lifeExp)) +
geom_boxplot() +
labs(x = "Continent", y = "Life expectancy (years)",
title = "Life expectancy by continent")
```

Some people prefer comparing a numerical variable between different levels of a categorical variable, in this case comparing life expectancy between different continents, using a boxplot over a faceted histogram as we can make quick comparisons with single horizontal lines. For example, we can see that even the country with the highest life expectancy in Africa is still lower than all countries in Oceania.

It’s important to remember however that the solid lines in the middle of the boxes correspond to the medians (i.e. the middle value) rather than the mean (the average). So, for example, if you look at Asia, the solid line denotes the median life expectancy of around 72 years, indicating to us that half of all countries in Asia have a life expectancy below 72 years whereas half of all countries in Asia have a life expectancy above 72 years. Furthermore, note that:

- Africa and Asia have much more spread/variation in life expectancy as indicated by the interquartile range (the height of the boxes).
- Oceania has almost no spread/variation, but this might in large part be due to the fact there are only two countries in Oceania: Australia and New Zealand.

Now, let’s start making comparisons of life expectancy *between* continents. Let’s use Africa as a *baseline for comparsion*. Why Africa? Only because it happened to be first alphabetically, we could have just as appropriately used the Americas as the baseline for comparison. Using the “eyeball test” (just using our eyes to see if anything stands out), we make the following observations about differences in median life expectancy compared to the baseline of Africa:

- The median life expectancy of the Americas is roughly 20 years greater.
- The median life expectancy of Asia is roughly 20 years greater.
- The median life expectancy of Europe is roughly 25 years greater.
- The median life expectancy of Oceania is roughly 27.8 years greater.

Let’s remember these four differences vs Africa corresponding to the Americas, Asia, Europe, and Oceania: 20, 20, 25, 27.8.

*Learning check*

**(LC6.4)** Conduct a new exploratory data analysis with the same explanatory variable \(x\) being `continent`

but with `gdpPercap`

as the new outcome variable \(y\). Remember, this involves three things:

- Looking at the raw values
- Computing summary statistics of the variables of interest.
- Creating informative visualizations

What can you say about the differences in GDP per capita between continents based on this exploration?

### 6.2.2 Linear regression

In Subsection 6.1.2 we introduced *simple* linear regression, which involves modeling the relationship between a numerical outcome variable \(y\) as a function of a numerical explanatory variable \(x\), in our life expectancy example, we now have a categorical explanatory variable \(x\) `continent`

. While we still can fit a regression model, given our categorical explanatory variable we no longer have a concept of a “best-fitting” line, but rather “differences relative to a baseline for comparison.”

Before we fit our regression model, let’s create a table similar to Table 6.6, but

- Report the mean life expectancy for each continent.
- Report the difference in mean life expectancy
*relative*to Africa’s mean life expectancy of 54.806 in the column “mean vs Africa”; this column is simply the “mean” column minus 54.806.

Think back to your observations from the eyeball test of Figure 6.15 at the end of the last subsection. The column “mean vs Africa” is the same idea of comparing a summary statistic to a baseline for comparison, in this case the countries of Africa, but using means instead of medians.

continent | mean | mean vs Africa |
---|---|---|

Africa | 54.8 | 0.0 |

Americas | 73.6 | 18.8 |

Asia | 70.7 | 15.9 |

Europe | 77.6 | 22.8 |

Oceania | 80.7 | 25.9 |

Now, let’s use the `get_regression_table()`

function we introduced in Section 6.1.2 to get the *regression table* for `gapminder2007`

analysis:

```
lifeExp_model <- lm(lifeExp ~ continent, data = gapminder2007)
get_regression_table(lifeExp_model)
```

term | estimate | std_error | statistic | p_value | lower_ci | upper_ci |
---|---|---|---|---|---|---|

intercept | 54.8 | 1.02 | 53.45 | 0 | 52.8 | 56.8 |

continentAmericas | 18.8 | 1.80 | 10.45 | 0 | 15.2 | 22.4 |

continentAsia | 15.9 | 1.65 | 9.68 | 0 | 12.7 | 19.2 |

continentEurope | 22.8 | 1.70 | 13.47 | 0 | 19.5 | 26.2 |

continentOceania | 25.9 | 5.33 | 4.86 | 0 | 15.4 | 36.5 |

Just as before, we have the `term`

and `estimates`

columns of interest, but unlike before, we now have 5 rows corresponding to 5 outputs in our table: an intercept like before, but also `continentAmericas`

, `continentAsia`

, `continentEurope`

, and `continentOceania`

. What are these values? First, we must describe the equation for fitted value \(\widehat{y}\), which is a little more complicated when the \(x\) explanatory variable is categorical:

\[ \begin{align} \widehat{\text{life exp}} &= b_0 + b_{\text{Amer}}\cdot\mathbb{1}_{\mbox{Amer}}(x) + b_{\text{Asia}}\cdot\mathbb{1}_{\mbox{Asia}}(x) + b_{\text{Euro}}\cdot\mathbb{1}_{\mbox{Euro}}(x) + b_{\text{Ocean}}\cdot\mathbb{1}_{\mbox{Ocean}}(x)\\ &= 54.8 + 18.8\cdot\mathbb{1}_{\mbox{Amer}}(x) + 15.9\cdot\mathbb{1}_{\mbox{Asia}}(x) + 22.8\cdot\mathbb{1}_{\mbox{Euro}}(x) + 25.9\cdot\mathbb{1}_{\mbox{Ocean}}(x) \end{align} \]

Let’s break this down. First, \(\mathbb{1}_{A}(x)\) is what’s known in mathematics as an “indicator function” that takes one of two possible values:

\[ \mathbb{1}_{A}(x) = \left\{ \begin{array}{ll} 1 & \text{if } x \text{ is in } A \\ 0 & \text{if } \text{otherwise} \end{array} \right. \]

In a statistical modeling context this is also known as a “dummy variable”. In our case, let’s consider the first such indicator variable:

\[ \mathbb{1}_{\mbox{Amer}}(x) = \left\{ \begin{array}{ll} 1 & \text{if } \text{country } x \text{ is in the Americas} \\ 0 & \text{otherwise}\end{array} \right. \]

Now let’s interpret the terms in the estimate column of the regression table. First \(b_0 =\) `intercept = 54.8`

corresponds to the mean life expectancy for countries in Africa, since for country \(x\) in Africa we have the following equation:

\[ \begin{align} \widehat{\text{life exp}} &= b_0 + b_{\text{Amer}}\cdot\mathbb{1}_{\mbox{Amer}}(x) + b_{\text{Asia}}\cdot\mathbb{1}_{\mbox{Asia}}(x) + b_{\text{Euro}}\cdot\mathbb{1}_{\mbox{Euro}}(x) + b_{\text{Ocean}}\cdot\mathbb{1}_{\mbox{Ocean}}(x)\\ &= 54.8 + 18.8\cdot\mathbb{1}_{\mbox{Amer}}(x) + 15.9\cdot\mathbb{1}_{\mbox{Asia}}(x) + 22.8\cdot\mathbb{1}_{\mbox{Euro}}(x) + 25.9\cdot\mathbb{1}_{\mbox{Ocean}}(x)\\ &= 54.8 + 18.8\cdot 0 + 15.9\cdot 0 + 22.8\cdot 0 + 25.9\cdot 0\\ &= 54.8 \end{align} \]

i.e. All four of the indicator variables are equal to 0. Recall we stated earlier that we would treat Africa as the baseline for comparison group. Furthermore, this value corresponds to the group mean life expectancy for all African countries in Table 6.7.

Next, \(b_{\text{Amer}}\) = `continentAmericas = 18.8`

is the difference in mean life expectancies of countries in the Americas relative to Africa, or in other words, on average countries in the Americas had life expectancy 18.8 years greater. The fitted value yielded by this equation is:

\[ \begin{align} \widehat{\text{life exp}} &= b_0 + b_{\text{Amer}}\cdot\mathbb{1}_{\mbox{Amer}}(x) + b_{\text{Asia}}\cdot\mathbb{1}_{\mbox{Asia}}(x) + b_{\text{Euro}}\cdot\mathbb{1}_{\mbox{Euro}}(x) + b_{\text{Ocean}}\cdot\mathbb{1}_{\mbox{Ocean}}(x)\\ &= 54.8 + 18.8\cdot\mathbb{1}_{\mbox{Amer}}(x) + 15.9\cdot\mathbb{1}_{\mbox{Asia}}(x) + 22.8\cdot\mathbb{1}_{\mbox{Euro}}(x) + 25.9\cdot\mathbb{1}_{\mbox{Ocean}}(x)\\ &= 54.8 + 18.8\cdot 1 + 15.9\cdot 0 + 22.8\cdot 0 + 25.9\cdot 0\\ &= 54.8 + 18.8\\ &= 72.9 \end{align} \]

i.e. in this case, only the indicator function \(\mathbb{1}_{\mbox{Amer}}(x)\) is equal to 1, but all others are 0. Recall that 72.9 corresponds to the group mean life expectancy for all countries in the Americas in Table 6.7.

Similarly, \(b_{\text{Asia}}\) = `continentAsia = 15.9`

is the difference in mean life expectancies of Asian countries relative to Africa countries, or in other words, on average countries in the Asia had life expectancy 18.8 years greater than Africa. The fitted value yielded by this equation is:

\[ \begin{align} \widehat{\text{life exp}} &= b_0 + b_{\text{Amer}}\cdot\mathbb{1}_{\mbox{Amer}}(x) + b_{\text{Asia}}\cdot\mathbb{1}_{\mbox{Asia}}(x) + b_{\text{Euro}}\cdot\mathbb{1}_{\mbox{Euro}}(x) + b_{\text{Ocean}}\cdot\mathbb{1}_{\mbox{Ocean}}(x)\\ &= 54.8 + 18.8\cdot\mathbb{1}_{\mbox{Amer}}(x) + 15.9\cdot\mathbb{1}_{\mbox{Asia}}(x) + 22.8\cdot\mathbb{1}_{\mbox{Euro}}(x) + 25.9\cdot\mathbb{1}_{\mbox{Ocean}}(x)\\ &= 54.8 + 18.8\cdot 0 + 15.9\cdot 1 + 22.8\cdot 0 + 25.9\cdot 0\\ &= 54.8 + 15.9\\ &= 70.7 \end{align} \]

i.e. in this case, only the indicator function \(\mathbb{1}_{\mbox{Asia}}(x)\) is equal to 1, but all others are 0. Recall that 70.7 corresponds to the group mean life expectancy for all countries in Asia in Table 6.7. The same logic applies to \(b_{\text{Euro}} = 22.8\) and \(b_{\text{Ocean}} = 25.9\); they correspond to the “offset” in mean life expectancy for countries in Europe and Oceania, relative to the mean life expectancy of the baseline group for comparison of African countries.

Let’s generalize this idea a bit. If we fit a linear regression model using a categorical explanatory variable \(x\) that has \(k\) levels, a regression model will return an intercept and \(k - 1\) “slope” coefficients. When \(x\) is a numerical explanatory variable the interpretation is of a “slope” coefficient, but when \(x\) is categorical the meaning is a little trickier. They are *offsets* relative to the baseline.

In our case, since there are \(k = 5\) continents, the regression model returns an intercept corresponding to the baseline for comparison Africa and \(k - 1 = 4\) slope coefficients corresponding to the Americas, Asia, Europe, and Oceania. Africa was chosen as the baseline by R for no other reason than it is first alphabetically of the 5 continents. You can manually specify which continent to use as baseline instead of the default choice of whichever comes first alphabetically, but we leave that to a more advanced course. (The `forcats`

package is particularly nice for doing this and we encourage you to explore using it.)

*Learning check*

**(LC6.5)** Fit a new linear regression using `lm(gdpPercap ~ continent, data = gapminder2007)`

where `gdpPercap`

is the new outcome variable \(y\). Get information about the “best-fitting” line from the regression table by applying the `get_regression_table()`

function. How do the regression results match up with the results from your exploratory data analysis above?

### 6.2.3 Observed/fitted values and residuals

Recall in Subsection 6.1.3 when we had a numerical explanatory variable \(x\), we defined:

- Observed values \(y\), or the observed value of the outcome variable
- Fitted values \(\widehat{y}\), or the value on the regression line for a given \(x\) value
- Residuals \(y - \widehat{y}\), or the error between the observed value and the fitted value

What do fitted values \(\widehat{y}\) and residuals \(y - \widehat{y}\) correspond to when the explanatory variable \(x\) is categorical? Let’s investigate these values for the first 10 countries in the `gapminder2007`

dataset:

country | continent | lifeExp | gdpPercap |
---|---|---|---|

Afghanistan | Asia | 43.8 | 975 |

Albania | Europe | 76.4 | 5937 |

Algeria | Africa | 72.3 | 6223 |

Angola | Africa | 42.7 | 4797 |

Argentina | Americas | 75.3 | 12779 |

Australia | Oceania | 81.2 | 34435 |

Austria | Europe | 79.8 | 36126 |

Bahrain | Asia | 75.6 | 29796 |

Bangladesh | Asia | 64.1 | 1391 |

Belgium | Europe | 79.4 | 33693 |

Recall the `get_regression_points()`

function we used in Subsection 6.1.3 to return

- the observed value of the outcome variable,
- all explanatory variables,
- fitted values, and
- residuals for all points in the regression. Recall that each “point”. In this case, each row corresponds to one of 142 countries in the
`gapminder2007`

dataset. They are also the 142 observations used to construct the boxplots in Figure 6.15.

```
regression_points <- get_regression_points(lifeExp_model)
regression_points
```

ID | lifeExp | continent | lifeExp_hat | residual |
---|---|---|---|---|

1 | 43.8 | Asia | 70.7 | -26.900 |

2 | 76.4 | Europe | 77.6 | -1.226 |

3 | 72.3 | Africa | 54.8 | 17.495 |

4 | 42.7 | Africa | 54.8 | -12.075 |

5 | 75.3 | Americas | 73.6 | 1.712 |

6 | 81.2 | Oceania | 80.7 | 0.515 |

7 | 79.8 | Europe | 77.6 | 2.180 |

8 | 75.6 | Asia | 70.7 | 4.907 |

9 | 64.1 | Asia | 70.7 | -6.666 |

10 | 79.4 | Europe | 77.6 | 1.792 |

Notice

- The fitted values
`lifeExp_hat`

\(\widehat{\text{lifeexp}}\). Countries in Africa have the same fitted value of 54.8, which is the mean life expectancy of Africa. Countries in Asia have the same fitted value of 70.7, which is the mean life expectancy of Asia. This similarly holds for countries in the Americas, Europe, and Oceania. - The
`residual`

column is simply \(y - \widehat{y}\) =`lifeexp - lifeexp_hat`

. These values can be interpreted as that particular country’s deviation from the mean life expectancy of the respective continent’s mean. For example, the first row of this dataset corresponds to Afghanistan, and the residual of \(-26.9 = 43.8 - 70.7\) is Afghanistan’s mean life expectancy minus the mean life expectancy of all Asian countries.

### 6.2.4 Residual analysis

Recall our discussion on residuals from Section 6.1.4 where our goal was to investigate whether or not there was a *systematic pattern* to the residuals. Ideally since residuals can be thought of as error, there should be no such pattern. While there are many ways to do such residual analysis, we focused on two approaches based on visualizations.

- A plot with residuals on the vertical axis and the predictor (in this case continent) on the horizontal axis
- A histogram of all residuals

First, let’s plot the residuals versus continent in Figure 6.16, but also let’s plot all 142 points with a little horizontal random jitter by setting the `width = 0.1`

parameter in `geom_jitter()`

:

```
ggplot(regression_points, aes(x = continent, y = residual)) +
geom_jitter(width = 0.1) +
labs(x = "Continent", y = "Residual") +
geom_hline(yintercept = 0, col = "blue")
```

We observe

- There seems to be a rough balance of both positive and negative residuals for all 5 continents.
- However, there is one clear outlier in Asia. It has the smallest residual, hence also has the smallest life expectancy in Asia.

Let’s investigate the 5 countries in Asia with the shortest life expectancy:

```
gapminder2007 %>%
filter(continent == "Asia") %>%
arrange(lifeExp)
```

country | continent | lifeExp | gdpPercap |
---|---|---|---|

Afghanistan | Asia | 43.8 | 975 |

Iraq | Asia | 59.5 | 4471 |

Cambodia | Asia | 59.7 | 1714 |

Myanmar | Asia | 62.1 | 944 |

Yemen, Rep. | Asia | 62.7 | 2281 |

This was the earlier identified residual for Afghanistan of -26.9. Unfortunately given recent geopolitical turmoil, individuals who live in Afghanistan and, in particular in 2007, have a drastically lower life expectancy.

Second, let’s look at a histogram of all 142 values of residuals in Figure 6.17. In this case, the residuals form a rather nice bell-shape, although there are a couple of very low and very high values at the tails. As we said previously, searching for patterns in residuals can be somewhat subjective, but ideally we hope there are no “drastic” patterns.

```
ggplot(regression_points, aes(x = residual)) +
geom_histogram(binwidth = 5, color = "white") +
labs(x = "Residual")
```

*Learning check*

**(LC6.6)** Continuing with our regression using `gdpPercap`

as the outcome variable and `continent`

as the explanatory variable, use the `get_regression_points()`

function to get the observed values, fitted values, and residuals for all 142 countries in 2007 and perform a residual analysis to look for any systematic patterns in the residuals. Is there a pattern? Please keep in mind that these types of questions are somewhat subjective and different people will most likely have different answers. The focus should be on being able to justify the conclusions made.

## 6.4 Conclusion

In this chapter, you’ve seen what we call “basic regression” when you only have one explanatory variable. In Chapter 7, we’ll study *multiple regression* where we have more than one explanatory variable! In particular, we’ll see why we’ve been conducting the residual analyses from Subsections 6.1.4 and 6.2.4. We are actually verifying some very important assumptions that must be met for the `std_error`

(standard error), `p_value`

, `lower_ci`

and `upper_ci`

(the end-points of the confidence intervals) columns in our regression tables to have valid interpretation. Again, don’t worry for now if you don’t understand what these terms mean. After the next chapter on multiple regression, we’ll dive in!

### 6.4.1 Script of R code

An R script file of all R code used in this chapter is available here.