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douconca

The douconca package

The aim of the douconca package is to help ecologists unravel trait-environment relationships from an abundance data table with associated multi-trait and multi-environment data tables. A popular method to such aim is RLQ (Dolédec et al. 1996; Dray et al. 2014), which also a three-tables method. RLQ is available in the R-package ade4(Dray and Dufour 2007; Thioulouse et al. 2018). The douconca package provides an alternative method, termed double-constrained correspondence analysis (dc-CA), which is a natural extension of the commonly used method of community-weighted means (CWMs) regression (Ter Braak, Šmilauer, and Dray 2018; Kleyer et al. 2012). As dc-CA is based on both regression analysis and ordination (factorial analysis), it allows for the usual forms of testing, model building, and of biplots of resulting scores. There are a number of recent applications that also contain discussion on the value of dc-CA compared to RLQ (Peng et al. 2021; Gobbi et al. 2022; Pinho et al. 2021), summarized in this document on ResearchGate.

The douconca package has a formula-interface to specify the dc-CA model, and scores, anova, plot and predict functions, mostly fairly similar to those in the vegan package (Oksanen et al. 2024) on to which douconca is based.

Double constained correspondence analysis

As RLQ, dc-CA seeks for an ordination (i.e. a low-dimensional representation of) of the multi-trait, multi-environment relationships, but dc-CA differs from RLQ in that dc-CA is based on regression with the traits and environmental variables as predictors, whereas RLQ is based on co-variance. The dc-CA method thus allows for variation-partitioning and the type of model-building that is familiar to users of regression analysis, whereas RLQ does not.

A dc-CA axis consists of two regression models (linear combinations), one of traits and the other of environmental predictors, the fitted values of which can be thought of as a composite trait and a composite environmental gradient. The response variables of these regressions are species niche centroids and CWMs of such composites. This circularity is typical for any eigenvalue ordination method. The linear combinations maximizes the fourth-corner correlation between the composite trait and composite environmental gradient. The dc-CA eigenvalues are squared fourth-corner correlations, but also variances, namely the amounts of variation in the abundance data that the consecutive axes explain (Ter Braak, Šmilauer, and Dray 2018).

Statistical testing is by the max test (Ter Braak, Cormont, and Dray 2012), evaluated by extensive simulation (Ter Braak 2019). This test combines two permutations tests, one permuting sites and the other permuting species, the maximum P-value of which is the final P-value. As in the vegan package, the permutations are specified via the permute package (Simpson 2022), so as to allow for analysis of hierarchical and nested data designs (Gobbi et al. 2022).

In douconca, a dc-CA models is specified by two formulas: a formula for the sites (rows) with environmental predictors and a formula for the species (columns) with trait predictors, which both may contain factors, quantitative variables and transformations thereof, and interactions, like in any (generalized) linear regression model. The formulas specify the constraints applied to the site and species scores; without constraints dc-CA is simply correspondence analysis.

The double constrained version of principal components analysis also exists and is available in the Canoco software (Ter Braak and Šmilauer 2018), but has less appeal in ecological applications as it lacks ecological realism, ease of interpretation and the link to methods, such as CWM-regression and fourth-corner correlation analysis, which have proven to be useful in trait-based ecology.

Example data and questions

We use the dune_trait_env data in the package to illustrate dc-CA. It consists of the abundances of 28 plant species in 20 meadows (plots, here called sites), trait data for these plant species and environmental data of these sites.

library(douconca)
data("dune_trait_env")
names(dune_trait_env)
#> [1] "comm"   "traits" "envir"
dim(dune_trait_env$comm[, -1]) ## without the variable "Sites"
#> [1] 20 28
dim(dune_trait_env$traits)
#> [1] 28 11
dim(dune_trait_env$envir)
#> [1] 20 10
names(dune_trait_env$traits)
#>  [1] "Species"      "Species_abbr" "SLA"          "Height"       "LDMC"        
#>  [6] "Seedmass"     "Lifespan"     "F"            "R"            "N"           
#> [11] "L"
names(dune_trait_env$envir)
#>  [1] "Sites"  "A1"     "Moist"  "Mag"    "Use"    "Manure" "X"      "Y"     
#>  [9] "X_lot"  "Y_lot"

There are five morphological traits (from the LEDA trait database) and four ecological traits (Ellenberg indicator values for moisture, acidity, nutrients and light).

There are five environmental variables and two sets of two spatial coordinates, which are approximately equal. The X and Y are the coordinates of the plot. The lot-variables are the center of the meadow where the sample has been taken.

The type of questions that dc-CA is able to address is:

How many dimenstions are needed to represent the major part of the trait-environment relations?
Is the trait-environment relationship statistically significant?
How many dimensions are statistically significant?
What is the importance of a variable in a dc-CA axis?
What is trait-structured variation and which of the trait sets has the larger such variation?
Which of the trait sets (morphological versus ecological) is more closely related to the environmental variables?

Basic analysis

The next code gives a basic dc-CA analysis. The response matrix or data frame must be numerical, with columns representing the species. The first variable (Sites) must therefore be deleted.

Y <- dune_trait_env$comm[, -1] # must delete "Sites"
mod <- dc_CA(formulaEnv = ~ A1 + Moist + Use + Manure + Mag,
             formulaTraits = ~ SLA + Height + LDMC + Seedmass + Lifespan,
             response = Y,
             dataEnv = dune_trait_env$envir,
             dataTraits = dune_trait_env$traits)
#> Step 1: the CCA ordination of the transposed matrix with trait constraints,
#>         useful in itself and also yielding CWMs of the orthonormalized traits for step 2.
#> Call: cca(formula = tY ~ SLA + Height + LDMC + Seedmass + Lifespan, data =
#> out0$data$dataTraits)
#> 
#> -- Model Summary --
#> 
#>               Inertia Proportion Rank
#> Total          2.3490     1.0000     
#> Constrained    0.6776     0.2885    5
#> Unconstrained  1.6714     0.7115   19
#> 
#> Inertia is scaled Chi-square
#> 
#> -- Eigenvalues --
#> 
#> Eigenvalues for constrained axes:
#>    CCA1    CCA2    CCA3    CCA4    CCA5 
#> 0.26839 0.19597 0.12356 0.07003 0.01967 
#> 
#> Eigenvalues for unconstrained axes:
#>    CA1    CA2    CA3    CA4    CA5    CA6    CA7    CA8 
#> 0.4386 0.2396 0.1938 0.1750 0.1429 0.1112 0.0854 0.0601 
#> (Showing 8 of 19 unconstrained eigenvalues)
#> 
#> Step 2: the RDA ordination of CWMs of the orthonormalized traits 
#>         of step 1 with environmental constraints:
#> Call: rda(formula = out1$CWMs_orthonormal_traits ~ A1 + Moist + Use +
#> Manure + Mag, data = out1$data$dataEnv)
#> 
#> -- Model Summary --
#> 
#>               Inertia Proportion Rank
#> Total          0.6776     1.0000     
#> Constrained    0.4454     0.6573    5
#> Unconstrained  0.2322     0.3427    5
#> 
#> Inertia is variance
#> 
#> -- Eigenvalues --
#> 
#> Eigenvalues for constrained axes:
#>    RDA1    RDA2    RDA3    RDA4    RDA5 
#> 0.23680 0.10903 0.05934 0.03792 0.00233 
#> 
#> Eigenvalues for unconstrained axes:
#>     PC1     PC2     PC3     PC4     PC5 
#> 0.12017 0.05836 0.03455 0.01337 0.00575 
#> 
#> mean, sd, VIF and canonical coefficients with their optimistic [!] t-values:
#>         Avg    SDS    VIF   Regr1   tval1
#> A1     4.85 2.1240 1.6967 -0.0605 -0.9172
#> Moist  2.90 1.7578 1.7658  0.3250  4.8293
#> Use    1.90 0.7681 1.7825  0.0219  0.3239
#> Manure 1.75 1.4448 9.3847 -0.1444 -0.9306
#> MagBF  0.15 0.3571 4.5016 -0.0475 -0.4421
#> MagHF  0.25 0.4330 2.6715 -0.0156 -0.1890
#> MagNM  0.30 0.4583 9.5666  0.1622  1.0352
#>                        Avg     SDS    VIF   Regr1   tval1
#> SLA                24.6468  6.3438 1.1888 -0.8196 -3.6933
#> Height             25.1272 15.6848 1.3033 -0.1598 -0.6877
#> LDMC              244.5084 70.9729 1.1791 -0.0562 -0.2542
#> Seedmass            0.6543  0.6688 1.0784 -0.7586 -3.5896
#> Lifespanperennial   0.9607  0.1944 1.0964  0.1006  0.4722
#> 
#>                weighted variance
#> total                      2.349
#> traits_explain             0.678
#> env_explain                1.323
#> constraintsTE              0.445
#> attr(,"meaning")
#>                meaning                                                                
#> total          "total inertia (= weighted variation)"                                 
#> traits_explain "trait-constrained variation"                                          
#> env_explain    "environment-constrained variation"                                    
#> constraintsTE  "trait-constrained variation explained by the predictors in formulaEnv"

In douconca, dc-CA is calculated in two steps that provide useful information each. Step 1 of the dc-CA algorithm summarizes the canonical correspondence analysis (CCA) of the transposed response matrix on to the trait data using formulaTraits = ~ SLA + Height + LDMC + Seedmass + Lifespan. The morphological traits in this formula explain 28.85% of the total inertia (variance) in the abundance data Y. This inertia (0.6776) is called the trait-structured variation. Inertia is in general a weighted variance, but in this case it is thus unweighted as sites have equal weight in the analysis, because divideBySiteTotals is true by defaults. Formally, it is the total (unweighted) variance in the community weighted means of orthonormalized traits (the traits are orthonormalized in Step 1). The trait-structured variation is further analyzed in Step 2 using redundancy analysis (RDA). Step 2 shows that 65.73% of this variation can be explained by the environmental variables using formulaEnv = ~ A1 + Moist + Use + Manure + Mag. The constrained axes of this RDA are also the dc-CA eigenvalues:

mod$eigenvalues
#>      dcCA1      dcCA2      dcCA3      dcCA4      dcCA5 
#> 0.23680387 0.10903220 0.05933626 0.03791909 0.00232876

The first axis explains 53% of the trait-environment variance and this axis is dominated by moisture and by SLA and Seedmass, as judged by the size of their regression coefficient and (optimistic) t-value on this axis in the print of the model. The default plot shows the intra-set correlations of the variables with the axis, but t-values can be visualized with

plot(mod,gradient_description = "t")

Statistical testing

There are two-ways to statistically test the model: (1) the omnibus test (using all five dimensions) is obtained with anova(mod), giving a P-value of about 0.02 and (2) a test per dc-CA axis, obtained by

set.seed(1)
anova(mod, by = "axis")
#> $species
#> Species-level permutation test using dc-CA
#> Model: dc_CA(formulaEnv = ~A1 + Moist + Use + Manure + Mag, formulaTraits = ~SLA + Height + LDMC + Seedmass + Lifespan, response = Y, dataEnv = dune_trait_env$envir, dataTraits = dune_trait_env$traits) 
#> Residualized predictor permutation
#> 
#>          df ChiSquare       R2      F Pr(>F)  
#> dcCA1     1   0.23680 0.179002 5.9370  0.087 .
#> dcCA2     1   0.10903 0.082419 2.7336  0.476  
#> dcCA3     1   0.05934 0.044853 1.4877  0.760  
#> dcCA4     1   0.03792 0.028663 0.9507  0.816  
#> dcCA5     1   0.00233 0.001760 0.0584  1.000  
#> Residual 22   0.87749                         
#> ---
#> Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
#> 
#> $sites
#>          Df ChiSquare      R2       F Pr(>F)    
#> dcCA1     1  0.236804 0.34946 14.2776  0.001 ***
#> dcCA2     1  0.109032 0.16090  6.5739  0.075 .  
#> dcCA3     1  0.059336 0.08757  3.5776  0.409    
#> dcCA4     1  0.037919 0.05596  2.2863  0.676    
#> dcCA5     1  0.002329 0.00344  0.1404  1.000    
#> Residual 14  0.232199                           
#> ---
#> Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
#> 
#> $maxP
#> Max test combining the community- and species- level tests 
#> Model: dc_CA(formulaEnv = ~A1 + Moist + Use + Manure + Mag, formulaTraits = ~SLA + Height + LDMC + Seedmass + Lifespan, response = Y, dataEnv = dune_trait_env$envir, dataTraits = dune_trait_env$traits) 
#> 
#> Taken from the species-level test:
#> Residualized predictor permutation
#> Permutation: free
#> Number of permutations: 999
#> 
#>          df ChiSquare       R2      F Pr(>F)  
#> dcCA1     1   0.23680 0.179002 5.9370  0.087 .
#> dcCA2     1   0.10903 0.082419 2.7336  0.476  
#> dcCA3     1   0.05934 0.044853 1.4877  0.760  
#> dcCA4     1   0.03792 0.028663 0.9507  0.816  
#> dcCA5     1   0.00233 0.001760 0.0584  1.000  
#> Residual 22   0.87749                         
#> ---
#> Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1

In the test per axis, the first axis has P-values of 0.09 and 0.001 at the species- and site-level, respectively, so that the P-value of the max test is 0.09. A little more explanation may be instructive. The species-level test consists of testing the (weighted) regression of the species-niche-centroids with respect to orthonormalized environmental variables against the traits. The site-level test consists of testing the (in this case, unweighted) regression of the community-weighted means of orthonormalized traits against the environmental variables. Both tests are carried out by permutation, the first by permuting species in the trait data, the second by permuting sites in the environmental data. A new dc-CA is carried out for each permuted data set. For a full description see under Details in the help system.

Fitted values and predictions

There are three kinds of fitted values (and of predictions for new data):

fitted traits per site, obtained with predict(mod, type = "traits" )
fitted environmental values per species, obtained with predict(mod, type = "env")
fitted abundances, obtained with predict(mod, type = "response" )

The fitted traits per site are simply fitted community-weighted means and the fitted environmental values are fitted species-niche centroids. Note that 10% of the fitted abundance values is negative in our example. Negative values indicate likely absences or low abundance values of species with the specified traits and environmental values.

Which set of traits is most closely related to abundance and to the environment?

In this section, we pose the question whether the set of morphological (functional) traits is more or less related to species abundance and to the environmental variables than the set of ecological traits.

mod_e <-  dc_CA(formulaEnv = ~ A1 + Moist + Manure + Use + Mag,
                formulaTraits = ~ F + R + N + L,
                response = Y,
                dataEnv = dune_trait_env$envir,
                dataTraits = dune_trait_env$traits)
#> Step 1: the CCA ordination of the transposed matrix with trait constraints,
#>         useful in itself and also yielding CWMs of the orthonormalized traits for step 2.
#> Call: cca(formula = tY ~ F + R + N + L, data = out0$data$dataTraits)
#> 
#> -- Model Summary --
#> 
#>               Inertia Proportion Rank
#> Total          2.3490     1.0000     
#> Constrained    0.8701     0.3704    4
#> Unconstrained  1.4789     0.6296   19
#> 
#> Inertia is scaled Chi-square
#> 
#> -- Eigenvalues --
#> 
#> Eigenvalues for constrained axes:
#>   CCA1   CCA2   CCA3   CCA4 
#> 0.4771 0.3122 0.0580 0.0228 
#> 
#> Eigenvalues for unconstrained axes:
#>     CA1     CA2     CA3     CA4     CA5     CA6     CA7     CA8 
#> 0.27842 0.24457 0.18230 0.16241 0.14740 0.09916 0.09167 0.06649 
#> (Showing 8 of 19 unconstrained eigenvalues)
#> 
#> Step 2: the RDA ordination of CWMs of the orthonormalized traits 
#>         of step 1 with environmental constraints:
#> Call: rda(formula = out1$CWMs_orthonormal_traits ~ A1 + Moist + Manure +
#> Use + Mag, data = out1$data$dataEnv)
#> 
#> -- Model Summary --
#> 
#>               Inertia Proportion Rank
#> Total          0.8701     1.0000     
#> Constrained    0.6331     0.7277    4
#> Unconstrained  0.2369     0.2723    4
#> 
#> Inertia is variance
#> 
#> -- Eigenvalues --
#> 
#> Eigenvalues for constrained axes:
#>   RDA1   RDA2   RDA3   RDA4 
#> 0.3684 0.2452 0.0141 0.0054 
#> 
#> Eigenvalues for unconstrained axes:
#>     PC1     PC2     PC3     PC4 
#> 0.14787 0.06377 0.01573 0.00954 
#> 
#> mean, sd, VIF and canonical coefficients with their optimistic [!] t-values:
#>         Avg    SDS    VIF   Regr1   tval1
#> A1     4.85 2.1240 1.6967  0.1527  1.3122
#> Moist  2.90 1.7578 1.7658  0.4584  3.8618
#> Manure 1.75 1.4448 9.3847  0.0243  0.0888
#> Use    1.90 0.7681 1.7825  0.0886  0.7432
#> MagBF  0.15 0.3571 4.5016 -0.0086 -0.0452
#> MagHF  0.25 0.4330 2.6715  0.0136  0.0930
#> MagNM  0.30 0.4583 9.5666  0.1136  0.4110
#>      Avg    SDS    VIF   Regr1   tval1
#> F 6.1126 1.6685 1.1323  0.8158  6.0720
#> R 5.8061 1.1894 1.7564 -0.1812 -1.0830
#> N 5.1674 1.6303 1.7822 -0.1905 -1.1304
#> L 7.3839 0.8774 1.1378  0.3043  2.2594
#> 
#>                weighted variance
#> total                      2.349
#> traits_explain             0.870
#> env_explain                1.323
#> constraintsTE              0.633
#> attr(,"meaning")
#>                meaning                                                                
#> total          "total inertia (= weighted variation)"                                 
#> traits_explain "trait-constrained variation"                                          
#> env_explain    "environment-constrained variation"                                    
#> constraintsTE  "trait-constrained variation explained by the predictors in formulaEnv"

The entry traits_explain is 0.87, which is the variance in the abundance data that is explained by the traits. It can directly be compared to the corresponding entry in the previous model, which is 0.678. The entry constraintsTE is the variance in abundance data that is explained by traits and environmental variables jointly. Its value in the second model is higher than that in the first. On closer examination of the results, the second eigenvalue of the last model is even higher than the first one of the first model and, indeed, the first two dc-CA axes are significant as can be seen from an anova:

anova(mod_e, by = "axis")$max
#> Max test combining the community- and species- level tests 
#> Model: dc_CA(formulaEnv = ~A1 + Moist + Manure + Use + Mag, formulaTraits = ~F + R + N + L, response = Y, dataEnv = dune_trait_env$envir, dataTraits = dune_trait_env$traits) 
#> 
#> Taken from the community-level test.
#> 
#>          Df ChiSquare      R2       F Pr(>F)   
#> dcCA1     1   0.36835 0.42337 23.3220  0.002 **
#> dcCA2     1   0.24525 0.28188 15.5276  0.017 * 
#> dcCA3     1   0.01413 0.01624  0.8944  0.996   
#> dcCA4     1   0.00541 0.00622  0.3427  1.000   
#> Residual 15   0.23691                          
#> ---
#> Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1

The fourth-corner correlation of the best linear combination of the ecological traits with the best linear combination of the environmental variables is

round(sqrt(mod_e$eigenvalues[1]), 2)
#> dcCA1 
#>  0.61

compared to 0.49 for the best linear combination of the morphological traits. In conclusion, the ecological traits explain more of the abundance data and are closer related to the environmental variables.

Do the morphological traits contribute after accounting for the ecological traits?

Do the morphological traits carry important additional information on the species (beyond their ecological traits) for understanding which species occur where? (i.e. for understanding the species-environment relationships). To address this question, specify the ecological traits as Condition in the trait formula and perform an anova of the resulting model.

mod_mGe <-  dc_CA(formulaEnv = ~ A1 + Moist + Manure + Use + Mag,
                 formulaTraits = 
                   ~ SLA + Height + LDMC + Seedmass + Lifespan + Condition(F+R+N+L),
                 response = Y,
                 dataEnv = dune_trait_env$envir,
                 dataTraits = dune_trait_env$traits, verbose = FALSE)
anova(mod_mGe, by= "axis")$max
#> Max test combining the community- and species- level tests 
#> Model: dc_CA(formulaEnv = ~A1 + Moist + Manure + Use + Mag, formulaTraits = ~SLA + Height + LDMC + Seedmass + Lifespan + Condition(F + R + N + L), response = Y, dataEnv = dune_trait_env$envir, dataTraits = dune_trait_env$traits, verbose = FALSE) 
#> 
#> Taken from the species-level test:
#> Residualized predictor permutation
#> Permutation: free
#> Number of permutations: 999
#> 
#>          df ChiSquare       R2      F Pr(>F)
#> dcCA1     1   0.09333 0.135306 3.4800  0.183
#> dcCA2     1   0.07101 0.102951 2.6479  0.280
#> dcCA3     1   0.03381 0.049017 1.2607  0.837
#> dcCA4     1   0.00629 0.009115 0.2344  1.000
#> dcCA5     1   0.00259 0.003761 0.0967  1.000
#> Residual 18   0.48274

As jugded by the test of significance by axes, the morphological traits contribute little.

One trait: CWM regression without inflated type I error.

Introduction

CWM regression is know to suffer from serious type I error inflation in statistical testing (Peres-Neto, Dray, and Ter Braak 2017; Lepš and De Bello 2023). This section shows how to perform CWM regression of a single trait using dc-CA with a max test to guard against type I error inflation. This test does not suffer from the, sometimes extreme, conservativeness of the ZS (Zelený & Schaffers) modified test (Ter Braak, Peres-Neto, and Dray 2018; Lepš and De Bello 2023).

We also show the equivalence of the site-level test with that of a CWM-regression and the equivalence of the dc-CA and CWM regression coefficients. On the way, we give examples of the scores and fCWM_SNC functions in the douconca package.

Testing the relationship between LDMC and the environmental variables

mod_LDMC <- dc_CA(formulaEnv = ~ A1 + Moist + Manure + Use + Mag,
                   formulaTraits = ~ LDMC,
                   response = Y, 
                   dataEnv = dune_trait_env$envir,
                   dataTraits = dune_trait_env$trait, verbose = FALSE)
anova(mod_LDMC)
#> $species
#> Species-level permutation test using dc-CA
#> Model: dc_CA(formulaEnv = ~A1 + Moist + Manure + Use + Mag, formulaTraits = ~LDMC, response = Y, dataEnv = dune_trait_env$envir, dataTraits = dune_trait_env$trait, verbose = FALSE) 
#> Residualized predictor permutation
#> 
#>          df ChiSquare       R2      F Pr(>F)
#> dcCA      1   0.05605 0.042368 1.1503  0.396
#> Residual 26   1.26686                       
#> 
#> $sites
#>          Df ChiSquare      R2      F Pr(>F)  
#> dcCA1     7  0.056048 0.67074 3.4922  0.028 *
#> Residual 12  0.027513                        
#> ---
#> Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
#> 
#> $maxP
#> Max test combining the community- and species- level tests 
#> Model: dc_CA(formulaEnv = ~A1 + Moist + Manure + Use + Mag, formulaTraits = ~LDMC, response = Y, dataEnv = dune_trait_env$envir, dataTraits = dune_trait_env$trait, verbose = FALSE) 
#> 
#> Taken from the species-level test:
#> Residualized predictor permutation
#> Permutation: free
#> Number of permutations: 999
#> 
#>          df ChiSquare       R2      F Pr(>F)
#> dcCA      1   0.05605 0.042368 1.1503  0.396
#> Residual 26   1.26686

The P-values of the species-level and site-level permutation tests are 0.396 and 0.028, respectively, so that the final P-value is 0.396. There is thus no evidence that the trait LDMC is related to the environmental variables in the model.

We now show that performing CWM-regression only would lead to the opposite conclusion. For this, we first calculate the CWMs of LDMC, using the function fCWM_SNC, the arguments of which are similar to that of the dc_CA function.

CWMSNC_LDMC <- fCWM_SNC(formulaEnv = ~ A1 + Moist + Manure + Use + Mag,
                      formulaTraits = ~ LDMC,
                      response = Y, 
                      dataEnv = dune_trait_env$envir,
                      dataTraits = dune_trait_env$trait, verbose = FALSE)

The result, CWMSNC_LDMC, is a list containing the CWMs of LDMC, among other items. We combine the (community-weighted) mean LDMC to the environmental data, apply linear regresion and compare the model with the null model using anova.

envCWM <- cbind(dune_trait_env$envir, CWMSNC_LDMC$CWM)
lmLDMC <- lm(LDMC ~ A1 + Moist + Manure + Use + Mag, data = envCWM)
anova(lmLDMC, lm(LDMC ~ 1, data = envCWM))
#> Analysis of Variance Table
#> 
#> Model 1: LDMC ~ A1 + Moist + Manure + Use + Mag
#> Model 2: LDMC ~ 1
#>   Res.Df    RSS Df Sum of Sq      F Pr(>F)  
#> 1     12 2771.8                             
#> 2     19 8418.3 -7   -5646.5 3.4922 0.0279 *
#> ---
#> Signif. codes:  0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1

resulting in a P-value of 0.0279, which is in agreement with the P-value of the site-level permutation test of this model. CWM-regression of LDMC shows evidence for a relationship with the environmental variables whereas there is in fact very little evidence as shown by dc-CA.

The coefficients of a CWM-regression are proportional to those of dc-CA

The introduction said that dc-CA extends CWM-regression to multiple traits. We now show that the regression coefficients issued by dc-CA with a single trait are, up to a scaling constant, identical to those of a linear CWM-regression of this trait.

We first extract the regression coefficients from the dc-CA model using the scores function. The second line calculates the regression coefficients by dividing the standardize regression coefficients from dc_CA by the standard deviation of each environmental variable.

(regr_table <- scores(mod_LDMC, display = "reg"))
#>         Avg       SDS      VIF       dcCA1
#> A1     4.85 2.1240292 1.696694 -0.16636060
#> Moist  2.90 1.7578396 1.765817 -0.02346540
#> Manure 1.75 1.4448183 9.384723  0.78784718
#> Use    1.90 0.7681146 1.782458 -0.33963301
#> MagBF  0.15 0.3570714 4.501582  0.25168168
#> MagHF  0.25 0.4330127 2.671474  0.09905591
#> MagNM  0.30 0.4582576 9.566575  0.71778929
#> attr(,"meaning")
#> [1] "mean, sd, VIF, standardized regression coefficients."
coefs_LDMC_dcCA <- regr_table[, "dcCA1"] / regr_table[, "SDS"]
range(coef(lmLDMC)[-1] / coefs_LDMC_dcCA)
#> [1] 34.53293 34.53293

The result shows that the two sets of coefficients are equal up to a constant of proportionality, here 154.4359. The t-values are also equal:

cbind(summary(lmLDMC)$coefficients[-1, "t value", drop = FALSE],
scores(mod_LDMC, display = "tval"))
#>           t value      dcCA1
#> A1     -1.2978033 -1.2978033
#> Moist  -0.1794383 -0.1794383
#> Manure  2.6133127  2.6133127
#> Use    -2.5849991 -2.5849991
#> MagBF   1.2053943  1.2053943
#> MagHF   0.6158360  0.6158360
#> MagNM   2.3581903  2.3581903

References

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Dray, Stéphane, Philippe Choler, Sylvain Dolédec, Pedro R Peres-Neto, Wilfried Thuiller, Sandrine Pavoine, and Cajo JF Ter Braak. 2014. “Combining the Fourth-Corner and the RLQ Methods for Assessing Trait Responses to Environmental Variation.” Ecology 95 (1): 14–21.

Dray, Stéphane, and Anne-Béatrice Dufour. 2007. “The Ade4 Package: Implementing the Duality Diagram for Ecologists.” Journal of Statistical Software 22: 1–20.

Gobbi, Mauro, Luca Corlatti, Marco Caccianiga, Cajo JF Ter Braak, and Luca Pedrotti. 2022. “Hay Meadows’ Overriding Effect Shapes Ground Beetle Functional Diversity in Mountainous Landscapes.” Ecosphere 13 (8): e4193.

Kleyer, Michael, Stéphane Dray, Francescode Bello, Jan Lepš, Robin J Pakeman, Barbara Strauss, Wilfried Thuiller, and Sandra Lavorel. 2012. “Assessing Species and Community Functional Responses to Environmental Gradients: Which Multivariate Methods?” Journal of Vegetation Science 23 (5): 805–21.

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Peng, Feng-Jiao, Cajo JF Ter Braak, Andreu Rico, and Paul J Van den Brink. 2021. “Double Constrained Ordination for Assessing Biological Trait Responses to Multiple Stressors: A Case Study with Benthic Macroinvertebrate Communities.” Science of the Total Environment 754: 142171.

Peres-Neto, Pedro R, Stéphane Dray, and Cajo JF Ter Braak. 2017. “Linking Trait Variation to the Environment: Critical Issues with Community-Weighted Mean Correlation Resolved by the Fourth-Corner Approach.” Ecography 40 (7): 806–16.

Pinho, Bruno X, Marcelo Tabarelli, Cajo JF ter Braak, S Joseph Wright, Vı́ctor Arroyo-Rodrı́guez, Maı́ra Benchimol, Bettina MJ Engelbrecht, et al. 2021. “Functional Biogeography of Neotropical Moist Forests: Trait–Climate Relationships and Assembly Patterns of Tree Communities.” Global Ecology and Biogeography 30 (7): 1430–46.

Simpson, Gavin L. 2022. Permute: Functions for Generating Restricted Permutations of Data. https://CRAN.R-project.org/package=permute.

Ter Braak, Cajo JF. 2019. “New Robust Weighted Averaging-and Model-Based Methods for Assessing Trait–Environment Relationships.” Methods in Ecology and Evolution 10 (11): 1962–71.

Ter Braak, Cajo JF, Anouk Cormont, and Stéphane Dray. 2012. “Improved Testing of Species Traits–Environment Relationships in the Fourth-Corner Problem.” Ecology 93 (7): 1525–26.

Ter Braak, Cajo JF, Pedro R Peres-Neto, and Stéphane Dray. 2018. “Simple Parametric Tests for Trait–Environment Association.” Journal of Vegetation Science 29 (5): 801–11.

Ter Braak, Cajo JF, and Petr Šmilauer. 2018. “Canoco Reference Manual and User’s Guide: Software for Ordination, Version 5.10.”

Ter Braak, Cajo JF, Petr Šmilauer, and Stéphane Dray. 2018. “Algorithms and Biplots for Double Constrained Correspondence Analysis.” Environmental and Ecological Statistics 25 (2): 171–97.

Thioulouse, Jean, Stéphane Dray, Anne-Béatrice Dufour, Aurélie Siberchicot, Thibaut Jombart, and Sandrine Pavoine. 2018. Multivariate Analysis of Ecological Data with Ade4. Springer.

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