---
title: "Using the loo package (version >= 2.0.0)"
author: "Aki Vehtari and Jonah Gabry"
date: "`r Sys.Date()`"
output:
  html_vignette:
    toc: yes
params:
  EVAL: !r identical(Sys.getenv("NOT_CRAN"), "true")
---
<!--
%\VignetteEngine{knitr::rmarkdown}
%\VignetteIndexEntry{Using the loo package}
-->
```{r, child="children/SETTINGS-knitr.txt"}
```

```{r, child="children/SEE-ONLINE.txt", eval = if (isTRUE(exists("params"))) !params$EVAL else TRUE}
```

# Introduction

This vignette demonstrates how to use the __loo__ package to carry out 
Pareto smoothed importance-sampling leave-one-out cross-validation (PSIS-LOO) 
for purposes of model checking and model comparison. 

In this vignette we can't provide all necessary background information on
PSIS-LOO and its diagnostics (Pareto $k$ and effective sample size), so we
encourage readers to refer to the following papers for more details:

* Vehtari, A., Gelman, A., and Gabry, J. (2017). Practical Bayesian model evaluation using leave-one-out cross-validation and WAIC. _Statistics and Computing_. 27(5), 1413--1432. \doi:10.1007/s11222-016-9696-4. Links: [published](https://link.springer.com/article/10.1007/s11222-016-9696-4) | [arXiv preprint](https://arxiv.org/abs/1507.04544).

* Vehtari, A., Simpson, D., Gelman, A., Yao, Y., and Gabry, J. (2019). Pareto smoothed importance sampling. [arXiv preprint arXiv:1507.02646](https://arxiv.org/abs/1507.02646).
 

# Setup

In addition to the __loo__ package, we'll also be using __rstanarm__ and 
__bayesplot__:

```{r setup, message=FALSE}
library("rstanarm")
library("bayesplot")
library("loo")
```


# Example: Poisson vs negative binomial for the roaches dataset

## Background and model fitting 

The Poisson and negative binomial regression models used below in our example, 
as well as the `stan_glm` function used to fit the models,
are covered in more depth in the __rstanarm__ vignette 
[_Estimating Generalized Linear Models for Count Data with rstanarm_](http://mc-stan.org/rstanarm/articles/count.html). In the rest of 
this vignette we will assume the reader is already familiar with these kinds of
models.


### Roaches data

The example data we'll use comes from Chapter 8.3 of [Gelman and Hill
(2007)](http://www.stat.columbia.edu/~gelman/arm/). We want to make inferences
about the efficacy of a certain pest management system at reducing the number of
roaches in urban apartments. Here is how Gelman and Hill describe the experiment
and data (pg. 161):

> the treatment and control were applied to 160 and 104 apartments, respectively, and the outcome measurement $y_i$ in each apartment $i$ was the number of roaches caught in a set of traps. Different apartments had traps for different numbers of days

In addition to an intercept, the regression predictors for the model are
`roach1`, the pre-treatment number of roaches (rescaled above to be in units of
hundreds), the treatment indicator `treatment`, and a variable indicating
whether the apartment is in a building restricted to elderly residents `senior`.
Because the number of days for which the roach traps were used is not the same
for all apartments in the sample, we use the `offset` argument to specify that
`log(exposure2)` should be added to the linear predictor.

```{r data}
# the 'roaches' data frame is included with the rstanarm package
data(roaches)
str(roaches)

# rescale to units of hundreds of roaches
roaches$roach1 <- roaches$roach1 / 100
```

### Fit Poisson model

We'll fit a simple Poisson regression model using the `stan_glm` function from
the __rstanarm__ package.

```{r count-roaches-mcmc, results="hide"}
fit1 <-
  stan_glm(
    formula = y ~ roach1 + treatment + senior,
    offset = log(exposure2),
    data = roaches,
    family = poisson(link = "log"),
    prior = normal(0, 2.5, autoscale = TRUE),
    prior_intercept = normal(0, 5, autoscale = TRUE),
    seed = 12345
  )
```

Usually we would also run posterior predictive checks as shown in the 
__rstanarm__ vignette 
[Estimating Generalized Linear Models for Count Data with rstanarm](http://mc-stan.org/rstanarm/articles/count.html), but 
here we focus only on methods provided by the __loo__ package.

<br>

## Using the __loo__ package for model checking and comparison

_Although cross-validation is mostly used for model comparison, it is also useful for model checking._

### Computing PSIS-LOO and checking diagnostics

We start by computing PSIS-LOO with the `loo` function. Since we fit our model
using __rstanarm__ we can use the `loo` method for `stanreg` objects (fitted
model objects from __rstanarm__), which doesn't require us to first extract the
pointwise log-likelihood values. If we had written our own Stan program instead
of using __rstanarm__ we would pass an array or matrix of log-likelihood values
to the `loo` function (see, e.g. `help("loo.array", package = "loo")`). We'll
also use the argument `save_psis = TRUE` to save some intermediate results to be
re-used later.

```{r loo1}
loo1 <- loo(fit1, save_psis = TRUE)
```

`loo` gives us warnings about the Pareto diagnostics, which indicate that for
some observations the leave-one-out posteriors are different enough from the
full posterior that importance-sampling is not able to correct the difference.
We can see more details by printing the `loo` object.

```{r print-loo1}
print(loo1)
```

The table shows us a summary of Pareto $k$ diagnostic, which is used to assess
the reliability of the estimates. In addition to the proportion of leave-one-out
folds with $k$ values in different intervals, the minimum of the effective
sample sizes in that category is shown to give idea why higher $k$ values are
bad. Since we have some $k>1$, we are not able to compute an estimate for the
Monte Carlo standard error (SE) of the expected log predictive density
(`elpd_loo`) and `NA` is displayed. (Full details on the interpretation of 
the Pareto $k$ diagnostics are available in the Vehtari, Gelman, and Gabry
(2017) and Vehtari, Simpson, Gelman, Yao, and Gabry (2019) papers referenced
at the top of this vignette.)

In this case the `elpd_loo` estimate should not be considered reliable. If we
had a well-specified model we would expect the estimated effective number
of parameters (`p_loo`) to be smaller than or similar to the total number of
parameters in the model. Here `p_loo` is almost 300, which is about 70 times
the total number of parameters in the model, indicating severe model
misspecification.

### Plotting Pareto $k$ diagnostics

Using the `plot` method on our `loo1` object produces a plot of the $k$ values
(in the same order as the observations in the dataset used to fit the model) 
with horizontal lines corresponding to the same categories as in the
printed output above.

```{r plot-loo1, out.width = "70%"}
plot(loo1)
```

This plot is useful to quickly see the distribution of $k$ values, but it's
often also possible to see structure with respect to data ordering. In our case
this is mild, but there seems to be a block of data that is somewhat easier to
predict (indices around 90--150). Unfortunately even for these data points we
see some high $k$ values.

### Marginal posterior predictive checks

The `loo` package can be used in combination with the `bayesplot` package for
leave-one-out cross-validation marginal posterior predictive checks [Gabry et al
(2018)](https://arxiv.org/abs/1709.01449). LOO-PIT values are cumulative
probabilities for $y_i$ computed using the LOO marginal predictive distributions
$p(y_i|y_{-i})$. For a good model, the distribution of LOO-PIT values should be
uniform. In the following plot the distribution (smoothed density estimate) of
the LOO-PIT values for our model (thick curve) is compared to many
independently generated samples (each the same size as our dataset) from the
standard uniform distribution (thin curves).

```{r ppc_loo_pit_overlay}
yrep <- posterior_predict(fit1)

ppc_loo_pit_overlay(
  y = roaches$y,
  yrep = yrep,
  lw = weights(loo1$psis_object)
)
```

The excessive number of values close to 0 indicates that the model is
under-dispersed compared to the data, and we should consider a model that allows
for greater dispersion.

## Try alternative model with more flexibility

Here we will try [negative binomial](https://en.wikipedia.org/wiki/Negative_binomial_distribution)
regression, which is commonly used for overdispersed count data.  
Unlike the Poisson distribution, the negative binomial distribution 
allows the conditional mean and variance of $y$ to differ.

```{r count-roaches-negbin, results="hide"}
fit2 <- update(fit1, family = neg_binomial_2)
```

```{r loo2}
loo2 <- loo(fit2, save_psis = TRUE, cores = 2)
print(loo2)
```


```{r plot-loo2}
plot(loo2, label_points = TRUE)
```

Using the `label_points` argument will label any $k$ values larger than 0.7 with
the index of the corresponding data point. These high values are often the
result of model misspecification and frequently correspond to data points that
would be considered ``outliers'' in the data and surprising according to the
model [Gabry et al (2019)](https://arxiv.org/abs/1709.01449). Unfortunately,
while large $k$ values are a useful indicator of model misspecification, small
$k$ values are not a guarantee that a model is well-specified.

If there are a small number of problematic $k$
values then we can use a feature in __rstanarm__ that lets us refit the model
once for each of these problematic observations. Each time the model is refit,
one of the observations with a high $k$ value is omitted and the LOO
calculations are performed exactly for that observation. The results are then
recombined with the approximate LOO calculations already carried out for the
observations without problematic $k$ values:

```{r reloo}
if (any(pareto_k_values(loo2) > 0.7)) {
  loo2 <- loo(fit2, save_psis = TRUE, k_threshold = 0.7)
}
print(loo2)
```

In the print output we can see that the Monte Carlo SE is small compared to
the other uncertainties. 

On the other hand, `p_loo` is about 7 and still a bit higher than the total
number of parameters in the model. This indicates that there is almost certainly
still some degree of model misspecification, but this is much better than the
`p_loo` estimate for the Poisson model.

For further model checking we again examine the LOO-PIT values.
```{r ppc_loo_pit_overlay-negbin}
yrep <- posterior_predict(fit2)
ppc_loo_pit_overlay(roaches$y, yrep, lw = weights(loo2$psis_object))
```

The plot for the negative binomial model looks better than the Poisson plot, but
we still see that this model is not capturing all of the essential features in
the data.


## Comparing the models on expected log predictive density

We can use the `loo_compare` function to compare our two models on 
expected log predictive density (ELPD) for new data:

```{r loo_compare}
loo_compare(loo1, loo2)
```

The difference in ELPD is much larger than several times the estimated standard
error of the difference again indicating that the negative-binomial model is
expected to have better predictive performance than the Poisson model. However,
according to the LOO-PIT checks there is still some misspecification, and a
reasonable guess is that a hurdle or zero-inflated model would be an improvement
(we leave that for another case study).


<br>

# References

Gabry, J., Simpson, D., Vehtari, A., Betancourt, M. and Gelman, A. (2019),
Visualization in Bayesian workflow. _J. R. Stat. Soc. A_, 182: 389-402. 
\doi:10.1111/rssa.12378. ([journal version](https://rss.onlinelibrary.wiley.com/doi/full/10.1111/rssa.12378), 
[arXiv preprint](https://arxiv.org/abs/1709.01449), 
[code on GitHub](https://github.com/jgabry/bayes-vis-paper))
<a id="gabry2019"></a>

Gelman, A. and Hill, J. (2007). _Data Analysis Using Regression and
Multilevel/Hierarchical Models._ Cambridge University Press, Cambridge, UK.

Vehtari, A., Gelman, A., and Gabry, J. (2017). Practical Bayesian model
evaluation using leave-one-out cross-validation and WAIC. _Statistics and
Computing_. 27(5), 1413--1432. \doi:10.1007/s11222-016-9696-4.
[online](https://link.springer.com/article/10.1007/s11222-016-9696-4), 
[arXiv preprint arXiv:1507.04544](https://arxiv.org/abs/1507.04544).

Vehtari, A., Simpson, D., Gelman, A., Yao, Y., and Gabry, J. (2019). Pareto smoothed importance sampling. [arXiv preprint arXiv:1507.02646](https://arxiv.org/abs/1507.02646).
