Exercise 1: Multinomial logit model
In mlogit: Multinomial Logit Models

knitr::opts_chunk$set(echo = TRUE, message = FALSE, warning = FALSE, widtht = 65)
options(width = 65)

@. The problem set uses data on choice of heating system in California houses. The data set Heating from the mlogit package contains the data in R format. The observations consist of single-family houses in California that were newly built and had central air-conditioning. The choice is among heating systems. Five types of systems are considered to have been possible:

gas central (gc),
gas room (gr),
electric central (ec),
electric room (er),
heat pump (hp).

There are 900 observations with the following variables:

idcase gives the observation number (1-900),
depvar identifies the chosen alternative (gc, gr, ec, er, hp),
ic.alt is the installation cost for the 5 alternatives,
oc.alt is the annual operating cost for the 5 alternatives,
income is the annual income of the household,
agehed is the age of the household head,
rooms is the number of rooms in the house,
region a factor with levels ncostl (northern coastal region), scostl (southern coastal region), mountn (mountain region), valley (central valley region).

Note that the attributes of the alternatives, namely, installation cost and operating cost, take a different value for each alternative. Therefore, there are 5 installation costs (one for each of the 5 systems) and 5 operating costs. To estimate the logit model, the researcher needs data on the attributes of all the alternatives, not just the attributes for the chosen alternative. For example, it is not sufficient for the researcher to determine how much was paid for the system that was actually installed (ie., the bill for the installation). The researcher needs to determine how much it would have cost to install each of the systems if they had been installed. The importance of costs in the choice process (i.e., the coefficients of installation and operating costs) is determined through comparison of the costs of the chosen system with the costs of the non-chosen systems.

For these data, the costs were calculated as the amount the system would cost if it were installed in the house, given the characteristics of the house (such as size), the price of gas and electricity in the house location, and the weather conditions in the area (which determine the necessary capacity of the system and the amount it will be run.) These cost are conditional on the house having central air-conditioning. (That's why the installation cost of gas central is lower than that for gas room: the central system can use the air-conditioning ducts that have been installed.)

In a logit model, each variable takes a different value in each alternative. So, in our case, for example, we want to know the coefficient of installation cost in the logit model of system choice. The variable installation cost in the model actually consists of five variables in the dataset: ic.gc, ic.gr, ic.ec, ic.er and ic.hp, for the installation costs of the five systems. In the current code, there are two variables in the logit model. The first variable is called ic for installation cost. This variable consists of five variables in the dataset: ic.gc in the first alternative, ic.gr in the second alternative, etc.

Run a model with installation cost and operating cost, without intercepts

(a) Do the estimated coefficients have the expected signs?

library("mlogit")
data("Heating", package = "mlogit")
H <- dfidx(Heating, choice = "depvar", varying = c(3:12))
m <- mlogit(depvar ~ ic + oc | 0, H)
summary(m)

Yes, they are negative as expected, meaning that as the cost of a system rises (and the costs of the other systems remain the same) the probability of that system being chosen falls.

(b) Are both coefficients significantly different from zero?

Yes, the t-statistics are greater than 1.96, which is the critical level for 95\% confidence level.

apply(fitted(m, outcome = FALSE), 2, mean)

Not very well. 63.67\% of the sample chose gc (as shown at the top of the summary) and yet the estimated model gives an average probability of only 51.695\%. The other alternatives are also fairly poorly predicted. We will find how to fix this problem in one of the models below.

(d) The ratio of coefficients usually provides economically meaningful information. The willingness to pay ($wtp$) through higher installation cost for a one-dollar reduction in operating costs is the ratio of the operating cost coefficient to the installation cost coefficient. What is the estimated $wtp$ from this model? Is it reasonable in magnitude?

$$ U = \beta_{ic} ic + \beta_{oc} oc $$

$$ dU = \beta_{ic} dic + \beta_{oc} doc = 0 \Rightarrow -\frac{dic}{doc}\mid_{dU=0}=\frac{\beta_{oc}}{\beta_{ic}} $$

coef(m)["oc"]/coef(m)["ic"]

The model implies that the decision-maker is willing to pay \$.73 (ie., 73 cents) in higher installation cost in order to reduce annual operating costs by \$1.

A \$1 reduction in annual operating costs recurs each year. It is unreasonable to think that the decision-maker is only willing to pay only 73 cents as a one-time payment in return for a \$1/year stream of saving. This unreasonable implication is another reason (along with the inaccurate average probabilities) to believe this model is not so good. We will find below how the model can be improved.

(e) We can use the estimated $wtp$ to obtain an estimate of the discount rate that is implied by the model of choice of operating system. The present value of the future operating costs is the discounted sum of operating costs over the life of the system: $PV=\sum_{t=1}^L\frac{OC}{(1+r)^t}$ where $r$ is the discount rate and $L$ being the life of the system. As $L$ rises, the $PV$ approaches $OC/r$. Therefore, for a system with a sufficiently long life (which we will assume these systems have), a one-dollar reduction in $OC$ reduces the present value of future operating costs by $(1/r)$. This means that if the person choosing the system were incurring the installation costs and the operating costs over the life of the system, and rationally traded-off the two at a discount rate of $r$, the decisionmaker's $wtp$ for operating cost reductions would be $(1/r)$. Given this, what value of $r$ is implied by the estimated $wtp$ that you calculated in part (c)? Is this reasonable?

$U=a LC$ where $LC$ is lifecycle cost, equal to the sum of installation cost and the present value of operating costs: $LC=IC+(1/r)OC$. Substituting, we have $U=aIC + (a/r)OC$.

The models estimates $a$ as $-0.00623$ and $a/r$ as $-0.00457$. So $r = a/(a/r)=-.000623/.00457 = 1.36$ or 136\% discount rate. This is not reasonable, because it is far too high.

@. Estimate a model that imposes the constraint that $r=0.12$ (such that $wtp=8.33$). Test the hypothesis that $r=0.12$.

To impose this constraint, we create a lifecycle cost that embodies the constraint $lcc=ic+oc/0.12$ and estimate the model with this variable.

H$lcc <- H$ic + H$oc / 0.12
mlcc <- mlogit(depvar ~ lcc | 0, H)
library("lmtest")
lrtest(m, mlcc)
qchisq(0.05, df = 1, lower.tail = FALSE)

We perform a likelihood ratio test. The $\ln L$ for this constrained model is $-1248.7$. The $\ln L$ for the unconstrained model is $-1095.2$. The test statistic is twice the difference in $\ln L$: $2(1248.7-1095.2)=307$. This test is for one restriction (ie a restiction on the relation of the coefficient of operating cost to that of installation cost.) We therefore compare $307$ with the critical value of chi-squared with $1$ degree of freedom. This critical value for 95\% confidence is $3.8$. Since the statistic exceeds the critical value, we reject the hypothesis that $r=0.12$.

@. Add alternative-specific constants to the model. With $J$ alternatives, at most $J-1$ alternative-specific constants can be estimated. The coefficients of $J-1$ constants are interpreted as relative to alternative $J$th alternative. Normalize the constant for the alternative hp to 0.

(a) How well do the estimated probabilities match the shares of customers choosing each alternative?

mc <- mlogit(depvar ~ ic + oc, H, reflevel = 'hp')
summary(mc)
apply(fitted(mc, outcome = FALSE), 2, mean)

Note that they match exactly: alternative-specific constants in a logit model insure that the average probabilities equal the observed shares.

(b) Calculate the $wtp$ and discount rate $r$ that is implied by the estimates. Are these reasonable?

wtp <- coef(mc)["oc"] / coef(mc)["ic"]
wtp
r <- 1 / wtp
r

The decision-maker is willing to pay \$4.56 for a \$1 year stream of savings. This implies $r = 0.22$. The decision-maker applies a 22\% discount rate. These results are certainly more reasonable that in the previous model. The decision-maker is still estimated to be valuing saving somewhat less than would seem rational (ie applying a higher discount rate than seems reasonable). However, we need to remember that the decision-maker here is the builder. If home buyers were perfectly informed, then the builder would adopt the buyer's discount rate. However, the builder would adopt a higher discount rate if home buyers were not perfectly informed about (or believed) the stream of saving.

(c) This model contains constants for all alternatives ec-er-gc-gr, with the constant for alternative hp normalized to zero. Suppose you had included constants for alternatives ec-er-gc-hp, with the constant for alternative gr normalized to zero. What would be the estimated coefficient of the constant for alternative gc? Figure this out logically rather than actually estimating the model.

We know that when the hp is left out, the constant for alternative gc is $1.71074$ meaning that the average impact of unicluded factors is $1.71074$ higher for alternative gc than for alternative hp. Similarly, the constant for alternative gr is $0.30777$. If gr were left out instead of hp, then all the constants would be relative to alternative gr. The constant for alternative gc would the be $1.71074-.30777=1.40297$. That is, the average impact of unincluded factors is $1.40297$ higher for alt gc than alt gr. Similarly for the other alternatives. Note the the constant for alt 5 would be $0-.30777=-.3077$, since hp is normalized to zero in the model with hp left out.

update(mc, reflevel = "gr")

@. Now try some models with sociodemographic variables entering.

(a) Enter installation cost divided by income, instead of installation cost. With this specification, the magnitude of the installation cost coefficient is inversely related to income, such that high income households are less concerned with installation costs than lower income households. Does dividing installation cost by income seem to make the model better or worse?

mi <- mlogit(depvar ~ oc + I(ic / income), H)
summary(mi)

The model seems to get worse. The $\ln L$ is lower (more negative) and the coefficient on installation cost becomes insignificant (t-stat below 2).

(b) Instead of dividing installation cost by income, enter alternative-specific income effects. What do the estimates imply about the impact of income on the choice of central systems versus room system? Do these income terms enter significantly?

mi2 <- mlogit(depvar ~ oc + ic | income, H, reflevel = "hp")

The model implies that as income rises, the probability of heat pump rises relative to all the others (since income in the heat pump alt is normalized to zero, and the others enter with negative signs such that they are lower than that for heat pumps. Also, as income rises, the probability of gas room drops relative to the other non-heat-pump systems (since it is most negative).

Do these income terms enter significantly? No. It seems that income doesn't really have an effect. Maybe this is because income is for the family that lives in the house, whereas the builder made decision of which system to install.

lrtest(mc, mi2)
waldtest(mc, mi2)
scoretest(mc, mi2)

I'm not going to give what I consider my best model: your ideas on what's best are what matter here.

We now are going to consider the use of logit model for prediction. Estimate a model with installation costs, operating costs, and alternative specific constants. Calculate the probabilities for each house explicitly. Check to be sure that the mean probabilities are the same as you got in exercise 4.

X <- model.matrix(mc)
alt <- idx(mc, 2)
chid <- idx(mc, 1)
eXb <- as.numeric(exp(X %*% coef(mc)))
SeXb <- tapply(eXb, chid, sum)
P <- eXb / SeXb[chid]
P <- matrix(P, ncol = 5, byrow = TRUE)
head(P)
apply(P, 2, mean)

This can be computed much more simply using the \Rf{fittedfunction, with the \Ra{outcome{fittedargument set to \Rv{FALSE so that the probabilities for all the alternatives (and not only the chosen one) is returned.

apply(fitted(mc, outcome = FALSE), 2, mean)

@. The California Energy Commission (CEC) is considering whether to offer rebates on heat pumps. The CEC wants to predict the effect of the rebates on the heating system choices of customers in California. The rebates will be set at 10\% of the installation cost. Using the estimated coefficients from the model in exercise 6, calculate new probabilities and predicted shares using the new installation cost of heat pump. How much do the rebates raise the share of houses with heat pumps?

Hn <- H
Hn[idx(Hn, 2) == "hp", "ic"] <- 0.9 * Hn[idx(Hn, 2) == "hp", "ic"]
apply(predict(mc, newdata = Hn), 2, mean)

We estimate the model with the actual costs. Then we change the costs and calculate probabilities with the new costs. The average probability is the predicted share for an alternative. At the original costs, the heat pump share is $0.0555$ (ie, about 5.5\%) This share is predicted to rise to $0.0645$ (about 6.5\%) when rebates are given.

@. Suppose a new technology is developed that provides more efficient central heating. The new technology costs \$200 more than the central electric system. However, it saves 25\% of the electricity, such that its operating costs are 75\% of the operating costs of ec. We want to predict the potential market penetration of this technology. Note that there are now six alternatives: the original five alternatives plus this new one. Calculate the probability and predict the market share (i.e., the average probability) for all six alternatives, using the model that is estimated on the original five alternatives. (Be sure to use the original installation cost for heat pumps, rather than the reduced cost in exercise 7.) What is the predicted market share for the new technology? From which of the original five systems does the new technology draw the most customers?

X <- model.matrix(mc)
Xn <- X[idx(mc, 2) == "ec",]
Xn[, "ic"] <- Xn[, "ic"] + 200
Xn[, "oc"] <- Xn[, "oc"] * 0.75
unchid <- unique(idx(mc, 1))
rownames(Xn) <- paste(unchid, 'new', sep = ".")
chidb <- c(chid, unchid)
X <- rbind(X, Xn)
X <- X[order(chidb), ]
eXb <- as.numeric(exp(X %*% coef(mc)))
SeXb <- as.numeric(tapply(eXb, sort(chidb), sum))
P <- eXb / SeXb[sort(chidb)]
P <- matrix(P, ncol = 6, byrow = TRUE)
apply(P, 2, mean)

The new technology captures a market share of 0.1036. That is, it gets slightly more than ten percent of the market.

It draws the same percent (about 10\%) from each system. This means that it draws the most in absolute terms from the most popular system, gas central. For example, gas central drops from to $0.637$ to $0.571$; this is an absolute drop of $0.637-0.571=0.065$ and a percent drop of $0.065/0.637$ about 10\%. Of the 10.36\% market share that is attained by the new technology, 6.5\% of it comes from gas central. The other systems drop by about the same percent, which is less in absolute terms.

The same percent drop for all systems is a consequence of the IIA property of logit. To me, this property seems unreasonable in this application. The new technology is a type of electric system. It seems reasonable that it would draw more from other electric systems than from gas systems. Models like nested logit, probit, and mixed logit allow more flexible, and in this case, more realistic substitution patterns.