`bamlss.Rmd`

The R package *bamlss* provides a modular computational framework for flexible Bayesian regression models (and beyond). The implementation follows the conceptional framework presented in Umlauf, Klein, and Zeileis (2018) and provides a modular “Lego toolbox” for setting up regression models. In this setting not only the response distribution or the regression terms are “Lego bricks” but also the estimation algorithm or the MCMC sampler.

The highlights of the package are:

- The usual R “look & feel” for regression modeling.
- Estimation of classic (GAM-type) regression models (Bayesian or frequentist).
- Estimation of flexible (GAMLSS-type) distributional regression models.
- An extensible “plug & play” approach for regression terms.
- Modular combinations of fitting algorithms and samplers.

Especially the last item is notable because the models in *bamlss* are not limited to a specific estimation algorithm but different engines can be plugged in without necessitating changes in other aspects of the model specification.

More detailed overviews and examples are provided in the articles:

The stable release version of *bamlss* is hosted on the Comprehensive R Archive Network (CRAN) at https://CRAN.R-project.org/package=bamlss and can be installed via

`install.packages("bamlss")`

The development version of *bamlss* is hosted on R-Forge at https://R-Forge.R-project.org/projects/bayesr/ in a Subversion (SVN) repository. It can be installed via

`install.packages("bamlss", repos = "http://R-Forge.R-project.org")`

This section gives a first quick overview of the functionality of the package and demonstrates that the usual “look & feel” when using well-established model fitting functions like `glm()`

is an elementary part of *bamlss*, i.e., first steps and basic handling of the package should be relatively simple. We illustrate the first steps with *bamlss* using a data set taken from the *Regression Book* (Fahrmeir et al. 2013) which is about prices of used VW Golf cars. The data is loaded with

```
## price age kilometer tia abs sunroof
## 1 7.30 73 10 12 yes yes
## 2 3.85 115 30 20 yes no
## 3 2.95 127 43 6 no yes
## 4 4.80 104 54 25 yes yes
## 5 6.20 86 57 23 no no
## 6 5.90 74 57 25 yes no
```

In this example the aim is to model the `price`

in 1000 Euro. Using *bamlss* a first Bayesian linear model could be set up by first specifying a model formula

`f <- price ~ age + kilometer + tia + abs + sunroof`

afterwards the fully Bayesian model using MCMC simulation is estimated by

Note that the default number of iterations for the MCMC sampler is 1200, the burnin-phase is 200 and thinning is 1 (see the manual of the default MCMC sampler `sam_GMCMC()`

). The reason is that during the modeling process, users usually want to obtain first results rather quickly. Afterwards, if a final model is estimated the number of iterations of the sampler is usually set much higher to get close to i.i.d. samples from the posterior distribution. To obtain reasonable starting values for the MCMC sampler we run a backfitting algorithm that optimizes the posterior mode. The *bamlss* package uses its own family objects, which can be specified as characters using the `bamlss()`

wrapper, in this case `family = "gaussian"`

(see also BAMLSS Families). In addition, the package also supports all families provided from the *gamlss* families.

The model summary gives

`summary(b1)`

```
##
## Call:
## bamlss(formula = f, family = "gaussian", data = Golf)
## ---
## Family: gaussian
## Link function: mu = identity, sigma = log
## *---
## Formula mu:
## ---
## price ~ age + kilometer + tia + abs + sunroof
## -
## Parametric coefficients:
## Mean 2.5% 50% 97.5% parameters
## (Intercept) 9.333318 8.526293 9.330200 10.173709 9.311
## age -0.038461 -0.045355 -0.038341 -0.031706 -0.038
## kilometer -0.009686 -0.012547 -0.009667 -0.007061 -0.010
## tia -0.005811 -0.022870 -0.005752 0.010105 -0.005
## absyes -0.240481 -0.492048 -0.237776 -0.003060 -0.238
## sunroofyes -0.024021 -0.300878 -0.025127 0.238145 -0.010
## -
## Acceptance probability:
## Mean 2.5% 50% 97.5%
## alpha 1 1 1 1
## ---
## Formula sigma:
## ---
## sigma ~ 1
## -
## Parametric coefficients:
## Mean 2.5% 50% 97.5% parameters
## (Intercept) -0.2457 -0.3479 -0.2465 -0.1274 -0.271
## -
## Acceptance probability:
## Mean 2.5% 50% 97.5%
## alpha 0.9703 0.7652 1.0000 1
## ---
## Sampler summary:
## -
## DIC = 408.9675 logLik = -201.0372 pd = 6.8932
## runtime = 0.665
## ---
## Optimizer summary:
## -
## AICc = 409.6319 edf = 7 logLik = -197.4745
## logPost = -252.2614 nobs = 172 runtime = 0.011
```

indicating high acceptance rates as reported by the `alpha`

parameter in the linear model output, which is a sign of good mixing of the MCMC chains. The mixing can also be inspected graphically by

`plot(b1, which = "samples")`

Note, for convenience we only show the traceplots of the intercepts. Considering significance of the estimated effects, only variables `tia`

and `sunroof`

seem to have no effect on `price`

since the credible intervals of estimated parameters contain zero. This information can also be extracted using the implemented `confint()`

method.

```
## 2.5% 97.5%
## mu.(Intercept) 8.52629257 10.173709336
## mu.age -0.04535461 -0.031705531
## mu.kilometer -0.01254739 -0.007060627
## mu.tia -0.02286985 0.010105028
## mu.absyes -0.49204765 -0.003060006
## mu.sunroofyes -0.30087769 0.238144948
## sigma.(Intercept) -0.34791813 -0.127380063
```

Since the prices cannot be negative, a possible consideration is to use a logarithmic transformation of the response `price`

```
set.seed(111)
f <- log(price) ~ age + kilometer + tia + abs + sunroof
b2 <- bamlss(f, family = "gaussian", data = Golf)
```

and compare the models using the `predict()`

method

`## [1] 0.5818444`

`## [1] 0.5410859`

indicating that the transformation seems to improve the model fit.

Instead of using linear effects, another option would be to use polynomial regression for covariates `age`

, `kilometer`

and `tia`

. A polynomial model using polynomials of order 3 is estimated with

```
set.seed(222)
f <- log(price) ~ poly(age, 3) + poly(kilometer, 3) + poly(tia, 3) + abs + sunroof
b3 <- bamlss(f, family = "gaussian", data = Golf)
```

Comparing the models using the `DIC()`

function

`DIC(b2, b3)`

```
## DIC pd
## b2 -15.19596 6.893153
## b3 -10.78925 13.186991
```

suggests that the polynomial model is slightly better. The effects can be inspected graphically, to better understand their influence on `price`

. Using the polynomial model, graphical inspections can be done using the `predict()`

method.

One major difference compared to other regression model implementations is that predictions can be made for single variables, only, where the user does not have to create a new data frame containing all variables. For example, posterior mean estimates and 95% credible intervals for variable `age`

can be obtained by

```
nd <- data.frame("age" = seq(min(Golf$age), max(Golf$age), length = 100))
nd$page <- predict(b3, newdata = nd, model = "mu", term = "age",
FUN = c95, intercept = FALSE)
head(nd)
```

```
## age page.2.5% page.Mean page.97.5%
## 1 65.00000 0.3085312 0.4849915 0.6592331
## 2 65.77778 0.3120472 0.4757206 0.6362999
## 3 66.55556 0.3167776 0.4663256 0.6152946
## 4 67.33333 0.3172396 0.4568109 0.5950657
## 5 68.11111 0.3201536 0.4471811 0.5742218
## 6 68.88889 0.3202023 0.4374406 0.5555146
```

Note that the prediction does not include the model intercept. Similarly for variables `kilometer`

and `tia`

```
nd$kilometer <- seq(min(Golf$kilometer), max(Golf$kilometer), length = 100)
nd$tia <- seq(min(Golf$tia), max(Golf$tia), length = 100)
nd$pkilometer <- predict(b3, newdata = nd, model = "mu", term = "kilometer",
FUN = c95, intercept = FALSE)
nd$ptia <- predict(b3, newdata = nd, model = "mu", term = "tia",
FUN = c95, intercept = FALSE)
```

Here, we need to specify for which `model`

predictions should be calculated, and if predictions only for variable `age`

are created, argument `term`

needs also be specified. Argument `FUN`

can be any function that should be applied on the samples of the linear predictor. For more examples see the documentation of the `predict.bamlss()`

method.

Then, the estimated effects can be visualized with

```
par(mfrow = c(1, 3))
ylim <- range(c(nd$page, nd$pkilometer, nd$ptia))
plot2d(page ~ age, data = nd, ylim = ylim)
plot2d(pkilometer ~ kilometer, data = nd, ylim = ylim)
plot2d(ptia ~ tia, data = nd, ylim = ylim)
```

The figure clearly shows the negative effect on the logarithmic `price`

for variable `age`

and `kilometer`

. The effect of `tia`

is not significant according the 95% credible intervals, since the interval always contains the zero horizontal line.

As a second startup on how to use *bamlss* for full distributional regression, we illustrate the basic steps on a small textbook example using the well-known simulated motorcycle accident data (Silverman 1985). The data contain measurements of the head acceleration (in \(g\), variable `accel`

) in a simulated motorcycle accident, recorded in milliseconds after impact (variable `times`

).

```
## times accel
## 1 2.4 0.0
## 2 2.6 -1.3
## 3 3.2 -2.7
## 4 3.6 0.0
## 5 4.0 -2.7
## 6 6.2 -2.7
```

To estimate a Gaussian location-scale model with \[ \texttt{accel} \sim \mathcal{N}(\mu = f(\texttt{times}), \log(\sigma) = f(\texttt{times})) \] we use the following model formula

where `s()`

is the smooth term constructor from the *mgcv* (Wood 2020). Note, that formulae are provided as `list`

s of formulae, i.e., each list entry represents one parameter of the response distribution. Also note that all smooth terms, i.e., `te()`

, `ti()`

, etc., are supported by *bamlss*. This way, it is also possible to incorporate user defined model terms. A fully Bayesian model is the estimated with

using the default of 1200 iterations of the MCMC sampler to obtain first results quickly (see the documentation `sam_GMCMC()`

for further details on tuning parameters). Note that per default `bamlss()`

uses a backfitting algorithm to compute posterior mode estimates, afterwards these estimates are used as starting values for the MCMC chains. The returned object is of class `"bamlss"`

for which generic extractor functions like `summary()`

, `plot()`

, `predict()`

, etc., are provided. For example, the estimated effects for distribution parameters `mu`

and `sigma`

can be visualized by

The model summary gives

`summary(b)`

```
##
## Call:
## bamlss(formula = f, family = "gaussian", data = mcycle)
## ---
## Family: gaussian
## Link function: mu = identity, sigma = log
## *---
## Formula mu:
## ---
## accel ~ s(times, k = 20)
## -
## Parametric coefficients:
## Mean 2.5% 50% 97.5% parameters
## (Intercept) -25.13 -29.36 -25.35 -20.34 -25.14
## -
## Acceptance probability:
## Mean 2.5% 50% 97.5%
## alpha 1 1 1 1
## -
## Smooth terms:
## Mean 2.5% 50% 97.5% parameters
## s(times).tau21 425657.47 175634.81 372121.15 914429.32 209325.0
## s(times).alpha 1.00 1.00 1.00 1.00 NA
## s(times).edf 14.24 12.64 14.22 15.97 13.6
## ---
## Formula sigma:
## ---
## sigma ~ s(times, k = 20)
## -
## Parametric coefficients:
## Mean 2.5% 50% 97.5% parameters
## (Intercept) 2.680 2.549 2.676 2.831 2.581
## -
## Acceptance probability:
## Mean 2.5% 50% 97.5%
## alpha 0.9664 0.7510 1.0000 1
## -
## Smooth terms:
## Mean 2.5% 50% 97.5% parameters
## s(times).tau21 1.458e+02 2.384e+01 1.213e+02 4.604e+02 81.406
## s(times).alpha 5.385e-01 7.903e-04 5.069e-01 1.000e+00 NA
## s(times).edf 9.415e+00 6.491e+00 9.500e+00 1.259e+01 8.675
## ---
## Sampler summary:
## -
## DIC = 1115.068 logLik = -545.2265 pd = 24.6149
## runtime = 1.956
## ---
## Optimizer summary:
## -
## AICc = 1123.881 edf = 24.2717 logLik = -531.975
## logPost = -747.4106 nobs = 133 runtime = 0.189
```

showing, e.g., the acceptance probabilities of the MCMC chains (`alpha`

), the estimated degrees of freedom of the optimizer and the successive sampler (`edf`

), the final AIC and DIC as well as parametric model coefficients (in this case only the intercepts). As mentioned in the first example, using MCMC involves convergence checks of the sampled parameters. The easiest diagnostics are traceplots

`plot(b, which = "samples")`

Note again that this call would show all traceplots, for convenience we only show the plots for the intercepts. In this case, the traceplots do not indicate convergence of the Markov chains for parameter `"mu"`

. To fix this, the number of iterations can be increased and also the burnin and thinning parameters can be adapted (see `sam_GMCMC()`

). Further inspections are the maximum autocorrelation of all parameters, using `plot.bamlss()`

setting argument `which = "max-acf"`

, besides other convergence diagnostics, e.g., diagnostics that are part of the *coda* package (Plummer et al. 2006).

Inspecting randomized quantile residuals (Dunn and Smyth 1996) is useful for judging how well the model fits to the data

Randomized quantile residuals are the default method in *bamlss*, which are computed using the CDF function of the corresponding family object.

The posterior mean including 95% credible intervals for new data based on MCMC samples for parameter \(\mu\) can be computed by

```
nd <- data.frame("times" = seq(2.4, 57.6, length = 100))
nd$ptimes <- predict(b, newdata = nd, model = "mu", FUN = c95)
plot2d(ptimes ~ times, data = nd)
```

and as above in the first example, argument `FUN`

can be any function, e.g., the `identity()`

function could be used to calculate other statistics of the distribution, e.g., plot the estimated densities for each iteration of the MCMC sampler for `times = 10`

and `times = 40`

:

```
## Predict for the two scenarios.
nd <- data.frame("times" = c(10, 40))
ptimes <- predict(b, newdata = nd, FUN = identity, type = "parameter")
## Extract the family object.
fam <- family(b)
## Compute densities.
dens <- list("t10" = NULL, "t40" = NULL)
for(i in 1:ncol(ptimes$mu)) {
## Densities for times = 10.
par <- list(
"mu" = ptimes$mu[1, i, drop = TRUE],
"sigma" = ptimes$sigma[1, i, drop = TRUE]
)
dens$t10 <- cbind(dens$t10, fam$d(mcycle$accel, par))
## Densities for times = 40.
par <- list(
"mu" = ptimes$mu[2, i, drop = TRUE],
"sigma" = ptimes$sigma[2, i, drop = TRUE]
)
dens$t40 <- cbind(dens$t40, fam$d(mcycle$accel, par))
}
## Visualize.
par(mar = c(4.1, 4.1, 0.1, 0.1))
col <- rainbow_hcl(2, alpha = 0.01)
plot2d(dens$t10 ~ accel, data = mcycle,
col.lines = col[1], ylab = "Density")
plot2d(dens$t40 ~ accel, data = mcycle,
col.lines = col[2], add = TRUE)
```

Dunn, Peter K., and Gordon K. Smyth. 1996. “Randomized Quantile Residuals.” *Journal of Computational and Graphical Statistics* 5 (3): 236–44.

Fahrmeir, Ludwig, Thomas Kneib, Stefan Lang, and Brian Marx. 2013. *Regression – Models, Methods and Applications*. Berlin: Springer-Verlag.

Plummer, Martyn, Nicky Best, Kate Cowles, and Karen Vines. 2006. “coda: Convergence Diagnosis and Output Analysis for MCMC.” *R News* 6 (1): 7–11. https://doi.org/10.18637/jss.v021.i11.

Silverman, B. W. 1985. “Some Aspects of the Spline Smoothing Approach to Non-Parametric Regression Curve Fitting.” *Journal of the Royal Statistical Society. Series B (Methodological)* 47 (1): 1–52.

Umlauf, Nikolaus, Nadja Klein, and Achim Zeileis. 2018. “BAMLSS: Bayesian Additive Models for Location, Scale and Shape (and Beyond).” *Journal of Computational and Graphical Statistics* 27 (3): 612–27. https://doi.org/10.1080/10618600.2017.1407325.

Umlauf, Nikolaus, Nadja Klein, Achim Zeileis, and Thorsten Simon. 2021a. *bamlss: Bayesian Additive Models for Location Scale and Shape (and Beyond)*. https://CRAN.R-project.org/package=bamlss.

———. 2021b. “bamlss: Bayesian Additive Models for Location Scale and Shape (and Beyond).” *Journal of Statistical Software* 100 (4): 1–53. https://doi.org/10.18637/jss.v100.i04.

Wood, S. N. 2020. *mgcv: GAMs with Gcv/Aic/Reml Smoothness Estimation and Gamms by Pql*. https://CRAN.R-project.org/package=mgcv.