DISCLAIMER: If the following text is not compiling for whatever reason, please use the README.pdf file available in the repo.
The package provides estimation and inferential procedures for rank-ordered logit model with agents with heterogeneous taste preferences.
We have $n$ i.i.d. random draws
$$
\mathcal{D}:=(Y_i,X_i)_{i=1}^{n}
$$
where $Y_i:=(Y_{i0},Y_{i1},\ldots,Y_{iJ})^\top, Y_{i\ell}=0,1,\ldots,J,$ is a vector of ranks and $C_i:=(X_{i0}, C_{i1},\ldots, C_{iJ})^\top \in \mathbb{R}^{(J+1)\cdot K},$ $C_{i\ell} \in\mathbb{R}^K$. Let the latent utility model (McFadden, 1974) be
$$
U_{ij}^\star = u_{ij} + \epsilon_{ij},\qquad \epsilon_{ij}\overset{\mathtt{iid}}{\sim}\mathsf{Gu}(0,1).
$$
For notational convenience, define the functions $r_i:{0,1,\ldots,J}\to{0,1,\ldots,J},i=1,\ldots,n$. Such functions map the rank $j\in{0,1,\ldots,J}$ into the corresponding item $r(j)\in{0,1,\ldots,J}$ according to individual $i$'s preferences. To clarify
$$
Y_{ij} = k\quad\iff\quad r_i(k)=j
$$
An observed ranking for a respondent implies a complete ordering of the underlying utilities. An individual will prefer an item with a higher utility over an item with a lower utility. If we observe a full ranking $r_i:=(r_i(0),r_i(1),\ldots,r_i(J))^\top$, we know that
$$
U_{ir_i(0)}^\star> U_{ir_i(1)}^\star>\cdots> U_{ir_i(J)}^\star.
$$
Therefore, the probability of observing a particular ranking $r_i$ is given by
$$
\mathbb{P}\left[r_i\mid \mathcal{D}\right] =\mathbb{P}\left[U_{ir_i(0)}^\star> U_{ir_i(1)}^\star>\cdots> U_{ir_i(J)}^\star\mid \mathcal{D}\right] =\prod_{j=0}^{J-1} \frac{\exp \left(u_{i r_{i}(j)}\right)}{\sum\limits_{j\leq \ell\leq J} \exp \left(u_{i r_{i}(\ell)}\right)}.
$$
In light of this, we can see that the rank-ordered logit is nothing else than a series of multinomial logit (MNL) models: when $j=0$ we considered a MNL the most preferred item; another MNL for the second-ranked item to be preferred over all items except the one with rank 1, and so on. Finally, the probability of a complete ranking is made up of the product of these separate MNL probabilities. The product contains only $J$ probabilities, because ranking the least preferred item is done with probability 1.
In its most general form, we allow the user to model $u_{i\ell}$ in the latent utility model as
$$
u_{i\ell} = X_{i\ell}^{\top} \boldsymbol{\beta}_{\mathtt{F}} + Z_i^{\top} \boldsymbol{\alpha}_{\ell,\mathtt{F}} +
W_{i\ell}^{\top} \boldsymbol{\beta}_i + V_i^{\top} \boldsymbol{\alpha}_{i\ell} + \delta_{\ell}
$$
An alternative, handier way to rewrite the model above is to define $Z_{i\ell}:=\sum\limits_{j=1}^JZ_i\times\mathbf{1}(j=\ell)$ and $V_{i\ell}:=\sum\limits_{j=1}^JV_i\times\mathbf{1}(j=\ell),\ell=1,2,\ldots,J$, and consider the equivalent model
$$
u_{i\ell}=X_{i\ell}^\top\boldsymbol{\beta}_{\mathtt{F}} + Z_{i\ell}^\top\boldsymbol{\alpha}_{\mathtt{F}} +
W_{i\ell}^\top\boldsymbol{\beta}_i + V_{i\ell}^\top\boldsymbol{\alpha}_{i} + \delta_\ell,
$$
where:
-
$X_{i\ell}$ are covariates varying at the unit-alternative level whose coefficients are modelled as fixed
-
$Z_{i}$ are covariates varying at the unit level whose coefficients are modelled as fixed
-
$W_{i\ell}$ are covariates varying at the unit-alternative level whose coefficients are modelled as random
-
$V_{i}$ are covariates varying at the unit level whose coefficients are modelled as random the random coefficients
- The heterogeneous taste coefficients are modeled as a joint multivariate normal and are i.i.d. across units with mean $\left[\boldsymbol{\alpha_{\mathtt{R}}}^\top,\boldsymbol{\beta_{\mathtt{R}}}^\top\right]^\top$ and variance $\boldsymbol{\Sigma}$.
-
$\delta_\ell$ are alternative-specific fixed effects
-
$\epsilon_{i\ell}\sim\mathsf{Gu}(0,1)$ are idiosyncratic i.i.d. shocks
Note that whenever $W_{i\ell}$ and $V_i$ are not specified estimates a standard rank-ordered logit with no heterogeneous preferences and the conditional choice probabilities are given by
$$
\mathbb{P}\left[r_i\mid \mathcal{D}\right] =\prod_{j=0}^{J-1} \frac{\exp \left(u_{i r_{i}(j)}\right)}{\sum\limits_{j\leq\ell\leq J} \exp \left(u_{i r_{i}(\ell)}\right)}.
$$
If instead agents are allowed to have heterogeneous taste, then
$$
\mathbb{P}[r_i\mid \mathcal{D}] = \int \prod_{j=0}^{J-1} \frac{\exp \left(u_{ir_i(j)}^\top(\beta_i)\right)}{\sum\limits_{j\leq \ell\leq J} \exp \left(u_{ir_i(\ell)}^\top(\beta_i)\right)} \phi(\beta_i;\beta,\Sigma) \mathrm{d} \beta_i.
$$
The parameter vector to be estimated is thus
$$
\theta = \left(\boldsymbol{\beta_\mathtt{F}}^\top,\boldsymbol{\beta_\mathtt{R}}^\top,\boldsymbol{\alpha_\mathtt{F}}^\top,\boldsymbol{\alpha_\mathtt{R}}^\top, \mathrm{vech}(\boldsymbol{\Sigma})^\top,{\delta}_{j=1}^J\right)^\top.
$$
The ideal maximum likelihood estimator is defined as
$$
\widehat{\theta}_{\mathtt{ML}}:=\mathrm{arg}\max_{\theta} \sum_{i=1}^n\log\int \prod_{j=0}^{J-1} \frac{\exp \left(u_{ir_i(j)}(\theta)\right)}{\sum\limits_{j\leq \ell\leq J} \exp \left(u_{ir_i(\ell)}(\theta)\right)} \phi(\beta_i;\beta_{\mathtt{R}},\Sigma) \mathrm{d} \beta_i.
$$
We approximate the integral via montecarlo as
$$
\widehat{\mathbb{P}}_{(\widehat{\beta},\widehat{\Sigma})}[r_i\mid \mathcal{D}]=\frac{1}{S}\sum_{i=1}^S \prod_{j=0}^{J-1} \frac{\exp \left(u_{ir_i(j)}(\theta,\beta_i^{(s)})\right)}{\sum\limits_{j\leq \ell\leq J} \exp \left(u_{ir_i(\ell)}(\theta,\beta_i^{(s)})\right)},
$$
where $\boldsymbol{\beta}i\overset{\mathtt{iid}}{\sim}\mathsf{N}(\widehat{\boldsymbol\beta}{\mathtt{R}},\widehat{\boldsymbol{\Sigma}})$.
You can install the development version of rcrologit from
GitHub with:
# install.packages("devtools")
devtools::install_github("filippopalomba/rcrologit")library(rcrologit)
data <- rcrologit_data
# Rank-ordered logit
dataprep <- dataPrep(data, idVar = "Worker_ID", rankVar = "rank",
altVar = "alternative",
covsInt.fix = list("Gender"),
covs.fix = list("log_Wage"), FE = c("Firm_ID"))
rologitEst <- rcrologit(dataprep)
# Rank-ordered logit
dataprep <- dataPrep(data, idVar = "Worker_ID", rankVar = "rank",
altVar = "alternative",
covsInt.het = list("Gender"),
covs.fix = list("log_Wage"), FE = c("Firm_ID"))
rologitEst <- rcrologit(dataprep, stdErr="skip")