- The conditional effect plots appear to have roughly similar inference compared to the model with autoregressive error covariance. The relative difference between the slopes of the iron and no-iron treatments is similar. The smoothers are very close to linear, so based on the plots I would argue that little is gained by fitting the GAMM. Your interpretation may vary!
- We use
`add_criterion()`

and`loo_compare()`

:

```
diggle_GAMM <- add_criterion(diggle_GAMM, 'loo')
loo_compare(diggle_GAMM, diggle_ar1)
```

```
## elpd_diff se_diff
## diggle_ar1 0.0 0.0
## diggle_GAMM -203.7 24.9
```

The AR1 model performs much better, providing additional evidence that there is not much benefit in introducing the added complexity of the GAMM in this case.

- Here are the models, with default priors and model fitting options (you may experiment with varying the defaults). I’ve loaded them from prefit model objects.

```
broadbalk_cosy <- brm(grain ~ year + cosy(time = year, gr = plot), data = broadbalk.wheat, file = 'fits/broadbalk_cosy')
broadbalk_ar1 <- brm(grain ~ year + ar(time = year, gr = plot, p = 1), data = broadbalk.wheat, file = 'fits/broadbalk_ar1')
```

- Again we use
`add_criterion()`

and`loo_compare()`

.

```
broadbalk_cosy <- add_criterion(broadbalk_cosy, 'loo')
broadbalk_ar1 <- add_criterion(broadbalk_ar1, 'loo')
loo_compare(broadbalk_cosy, broadbalk_ar1)
```

```
## elpd_diff se_diff
## broadbalk_cosy 0.0 0.0
## broadbalk_ar1 -149.2 20.0
```

The compound symmetry covariance is a better fit than the autoregressive. This makes sense because the time trends are capturing yearly environmental fluctuations. Each year is more or less unique and the weather in one year is not highly correlated with the previous. Thus, the autoregressive structure that models years closer in time as more closely correlated is a poor fit.

- Use
`summary(broadbalk_cosy)`

or`describe_posterior(broadbalk_cosy)`

to look at the parameter estimate for the slope and its 95% CI, or use`conditional_effects(broadbalk_cosy)`

to see a plot. We can see that there is evidence for a declining trend in grain yield over time.

`describe_posterior(broadbalk_cosy, test = 'p_map')`

```
## Summary of Posterior Distribution
##
## Parameter | Median | 95% CI | p (MAP) | Rhat | ESS
## --------------------------------------------------------------------
## (Intercept) | 19.75 | [16.87, 22.67] | < .001 | 1.001 | 4246.00
## year | -9.51e-03 | [-0.01, -0.01] | < .001 | 1.001 | 4277.00
```

- The heat map (fill color palette is optional) shows a strong trend for increased yield as you get closer to the upper right corner.

`ggplot(burgueno.rowcol, aes(x = col, y = row, fill = yield)) + geom_tile() + scale_fill_distiller(palette = 'Oranges', direction = 1)`

- Here are the models with default priors and model fitting options (again you may experiment with changing those). I’ve loaded them from prefit model objects.

```
burgueno_nonspatial <- brm(yield ~ gen, data = burgueno.rowcol, file = 'fits/burgueno_nonspatial')
burgueno_spatial <- brm(yield ~ gen + s(col, row, k = 10, bs = 'gp'), data = burgueno.rowcol, file = 'fits/burgueno_spatial')
```

- The residuals of the model that ignores the spatial trend still have a similar spatial trend to the observed data. The residuals of the spatial model look random.

```
burgueno.rowcol$residuals_nonspatial <- residuals(burgueno_nonspatial)[,1]
burgueno.rowcol$residuals_spatial <- residuals(burgueno_spatial)[,1]
ggplot(burgueno.rowcol, aes(x = col, y = row, fill = residuals_nonspatial)) + geom_tile() + scale_fill_distiller(palette = 'Greens', direction = 1)
```

`ggplot(burgueno.rowcol, aes(x = col, y = row, fill = residuals_spatial)) + geom_tile() + scale_fill_distiller(palette = 'Greens', direction = 1)`

As a bonus, here is code to calculate Moran’s I for both the models. We see there is fairly strong spatial autocorrelation in the first model’s residuals but not the second.

```
burgueno_inv_dist <- 1 / as.matrix(dist(cbind(burgueno.rowcol$col, burgueno.rowcol$row)))
diag(burgueno_inv_dist) <- 0
Moran.I(burgueno.rowcol$residuals_nonspatial, burgueno_inv_dist)
```

```
## $observed
## [1] 0.1279599
##
## $expected
## [1] -0.007874016
##
## $sd
## [1] 0.009038702
##
## $p.value
## [1] 0
```

`Moran.I(burgueno.rowcol$residuals_spatial, burgueno_inv_dist)`

```
## $observed
## [1] 0.009799946
##
## $expected
## [1] -0.007874016
##
## $sd
## [1] 0.009038264
##
## $p.value
## [1] 0.05052883
```