knitr::opts_chunk$set( collapse = TRUE, comment = "#>" )

Spatial autocorrelation can severely bias transfer function performance estimates. Telford and Birks (2009) suggested *h*-block cross-validation as a means of obtaining unbiased transfer function estimates. The problem is to estimate the optimal value of *h*: too small and the performance estimates are still over-optimistic, too large and the performance estimates are pessimistic. Trachsel and Telford (2015) presented three methods to estimate *h*:

- the performance of a transfer function on a spatially independent test set
- the autocorrelation in residuals of a weighted averaging transfer function
- Comparing the variance explained of a transfer function trained on random environmental data with similar spatial structure as the environmental data of influence with the correlation between the simulated data and the environmental data of influence.

library(palaeoSig) library(rioja) library(sp) library(gstat) library(dplyr) library(tibble) library(tidyr) library(purrr) library(ggplot2) # suppress warnings from MAT about duplicate samples (presumably 100% N. pachyderma) MAT <- function(...){ suppressWarnings(rioja::MAT(...)) }

We use the foraminifera dataset by Kucera et al. (2005). We split the dataset into two parts, a North Atlantic (NA) dataset (north of 3°N) and a South Atlantic (SA) data set (south of 3°S). We use the NA dataset as training set and the SA dataset as spatially independent test set.

#load data data(Atlantic) meta <- c("Core", "Latitude", "Longitude", "summ50") #N Atlantic N_Atlantic <- Atlantic %>% filter(Latitude > 3) N_Atlantic_meta <- N_Atlantic %>% select(one_of(meta)) %>% as.data.frame() # to keep rdist.earth happy N_Atlantic <- N_Atlantic %>% select(-one_of(meta)) #S Atlantic S_Atlantic <- Atlantic %>% filter(Latitude < -3) S_Atlantic_meta <- S_Atlantic %>% select(one_of(meta)) S_Atlantic <- S_Atlantic %>% select(-one_of(meta)) #calculating distances among the sampled points in the North Atlantic foraminifera data set geodist <- fields::rdist.earth(select(N_Atlantic_meta, Longitude, Latitude), miles = FALSE) #values of h for which h-block cross-validation is calculated threshs <- c(0.01, 100, 200, 400, 600, 700, 800, 900, 1000, 1200, 1400, 1600) #h-block cross-validation of the NA foraminifera dataset for different values of h res_h <- map_df(threshs, function(h){ mod <- MAT(N_Atlantic, N_Atlantic_meta$summ50, k = 5, lean = FALSE) mod <- crossval(mod, cv.method = "h-block", h.dist = geodist, h.cutoff = h) tibble(h = h, RMSE = performance(mod)$crossval["N05", "RMSE"], R2 = performance(mod)$crossval["N05", "R2"] ) })

First, we estimate the performance of the North Atlantic (NA) foraminifera training set when applied to the spatially independent data set from the South Atlantic (SA), which in our case contains the samples used by Kucera et al. (2005) that are situated south of 3°S.

#Leave-one-out cross-validated RMSEP using MAT with k = 5 round(res_h[1, 'RMSE'], 2) #Predicting the Sout Atlantic test set mod.NA <- MAT(N_Atlantic, N_Atlantic_meta$summ50, k = 5) pred.SA <- predict(mod.NA, newdata = S_Atlantic)$fit #Determining RMSEP of the SA test set rmse.mat <- sqrt(mean((pred.SA[, 1] - S_Atlantic_meta$summ50)^2)) #RMSEP of the SA test set using MAT with k = 5 round(rmse.mat, 2)

The RMSEP of the NA training set is `r round(res_h[1,'RMSE'], 2)`

while the RMSEP of the spatially independent SA data set is somewhat larger: `r round(rmse.mat,2)`

. This is indicative of spatial autocorrelation.
We have to find the the removal distance *h* at which the *h*-block cross-validated RMSEP and the RMSEP of the SA test set are similar.

est_h <- approx(y = res_h$h, x = res_h$RMSE, xout = rmse.mat)$y seg_dat <- tibble(x = c(-Inf, est_h), xend = c(est_h, est_h), y = c(rmse.mat, rmse.mat), yend = c(rmse.mat, -Inf) ) ggplot(res_h, aes(x = h, y = RMSE)) + geom_point() + geom_line() + geom_segment(aes(x = x, y= y, xend = xend, yend = yend), data = seg_dat, colour = "red") + labs(x = "h [km]", y = "RMSEP [°C]")

Using linear interpolation, an *h*-block distance of `r round(est_h, 2)`

km gives a cross-validated RMSEP equivalent to the the RMSEP of a spatially independent test set.

The second method proposed in Trachsel and Telford is to fit a variogram to detrended residuals of a weighted average model and use the range of the variogram as *h*.

#WA model modwa <- crossval(WA(sqrt(N_Atlantic), N_Atlantic_meta$summ50, mono = TRUE)) #residuals of the WA model wa.resid <- residuals(modwa, cv = TRUE) #detrend to remove edge effects (loess with span = 0.1) detrended_resid <- resid(loess(wa.resid[, 1] ~ N_Atlantic_meta$summ50, span = 0.1)) #copy meta data and add coordinate system N_Atlantic_meta_c <- N_Atlantic_meta coordinates(N_Atlantic_meta_c) <- ~ Longitude + Latitude proj4string(N_Atlantic_meta_c) <- CRS("+proj=longlat +datum=WGS84") #variogram of the detrended residuals of the WA model v <- variogram(detrended_resid ~ 1, data = N_Atlantic_meta_c) #Fitting a spherical variogram (partial sill, range and nugget are approximately estimated from the empirical variogram) vm <- fit.variogram(v, vgm(psill = 2, "Sph", range = 1500, nugget = 0.5)) plot(v, vm)

The estimated range of a spherical variogram model fitted to the detrended residual of a WA model is `r round(vm$range[2])`

km.

The third method suggested is based on simulated environmental variables with the same spatial structure as the environmental variable of interest. The transfer function performance (r^2^) of the simulated variable is compared to the r^2^ between the environmental variable of interest and the simulated variables. The optimal value for *h* is the value that minimises the difference these two r^2^.

To simulate the environmental variables of interest, we first have to estimate their spatial structure with a variogram and then use kriging with the variogram to simulate environmental variables with same spatial structure as the observed variable.

#Estimate the variogram model for the environmental variable of interest ve <- variogram(summ50 ~ 1, data = N_Atlantic_meta_c) vem <- fit.variogram(ve, vgm(40, "Mat", 5000, .1, kappa = 1.8)) plot(ve, vem) #Simulating environmental variables sim <- krige(sim ~ 1, locations = N_Atlantic_meta_c, dummy = TRUE, nsim = 100, beta = mean(N_Atlantic_meta[,"summ50"]), model = vem, newdata = N_Atlantic_meta_c) #convert spatialpointsdataframe back to a regular data.frame sim <- as.data.frame(sim) %>% select(-Longitude, -Latitude)

Running a MAT models for each simulation at each value of *h* would be very slow, but since the same analogues would be chosen for any environmental variable, we can make a much faster version of MAT.

#Function for h-block cross-validating several simulations at a time mat.h1 <- function (y, x, noanalogues, geodist, thresh) { if (!inherits(y, "dist")) { if (is.data.frame(y) || !(ncol(y) == nrow(y) & sum(diag(y)) == 0)) { y <- dist(sqrt(y))^2#squared chord distance } } y <- as.matrix(y) diag(y) <- Inf if (inherits(geodist, "dist")) geodist = as.matrix(geodist) sapply(seq_len(nrow(y)), function(n) {browser() exneigh <- geodist[n, ] >= thresh x2 <- x[exneigh, ] y2 <- y[n, ][exneigh] analogues <- which(rank(y2, ties.method = "random") <= noanalogues) colMeans(x2[analogues, ]) }) } #h-block cross-validation of the simulated variables simhr <- sapply(threshs, function(h) { hn <- mat.h1(N_Atlantic, sim, noanalogues = 5, geodist = geodist, thresh = h) diag(cor(t(hn), sim)^2) }) #Estimating squared correlation between environmental varible of interest and simulated variables sim.obs.r2 <- sapply(sim, cor, N_Atlantic_meta$summ50)^2 #Calculating sum of squares between the two squared correlations so.squares <- apply(simhr, 2, function(x){ sum((x - sim.obs.r2) ^ 2) })

simhr %>% as.data.frame() %>% set_names(threshs) %>% mutate(sim.obs.r2 = sim.obs.r2) %>% pivot_longer(cols = -sim.obs.r2, names_to = "h", values_to = "value") %>% mutate(h = factor(h, levels = threshs)) %>% ggplot(aes(x = sim.obs.r2, y = value)) + geom_point() + geom_abline() + facet_wrap(~h) + labs( x = "Simulated-observed environmental r²", y = "Transfer function r²")

tibble(threshs, so.squares) %>% ggplot(aes(x = threshs, y = so.squares)) + geom_point() + labs(x = "h km", y = "Sum of squares")

Following the rule described in Trachsel and Telford the value of *h* is estimated as *h* = `r res_h[min(which(so.squares < (min(so.squares) + 0.1 * range(so.squares)))), 'h']`

km.

Hence the three methods proposed result in similar values of *h*: *h* = `r round(est_h)`

km for the spatially independent test set, *h* = `r round(vm$range[2])`

km for the variogram range method and *h* = `r res_h[min(which(so.squares < (min(so.squares) + 0.1 * range(so.squares)))),'h']`

km for the variance explained method.

Kucera, M., Weinelt, M., Kiefer, T., Pflaumann, U., Hayes, A., Weinelt, M., Chen, M.-T., Mix, A.C., Barrows, T.T., Cortijo, E., Duprat, J., Juggins, S., Waelbroeck, C. 2005. Reconstruction of the glacial Atlantic and Pacific sea-surface temperatures from assemblages of planktonic foraminifera: multi-technique approach based on geographically constrained calibration datasets. *Quaternary Science Reviews* 24, 951-998 doi:10.1016/j.quascirev.2004.07.014.

Telford, R.J., Birks, H.J.B. 2009. Evaluation of transfer functions in spatially structured environments. *Quaternary Science Reviews* 28, 1309-1316 doi:10.1016/j.quascirev.2008.12.020.

Trachsel, M., Telford, R.J. (2016). Technical note: Estimating unbiased transfer function performances in spatially structured environments. submitted to: *Climate of the Past* 12, 1215-1223 doi:10.5194/cp-12-1215-2016

richardjtelford/palaeoSig documentation built on Dec. 28, 2019, 9:01 p.m.

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