In previous posts I have looked at how generalized additive models (GAMs) can be used to model nonlinear trends in time series data. At the time a number of readers commented that they were interested in modelling data that had more than just a trend component; how do you model data collected throughout the year over many years with a GAM? In this post I will show one way that I have found particularly useful in my research.
First an equation. If we think about a time series where observations were made on a number of occasions within any given year over a number of years, we may want to model the following features of the data
 any trend or long term change in the level of the time series, and
 any seasonal or withinyear variation, and
 any variation or interaction in the trend and seasonal features of the data,
I’m not going to cover point 3 in this post, but it is a relatively simple extension to what I will discuss here. So, considering points 1 and 2 only, we need an equation that describes this model
[ y = 0 + f{}(x_1) + f_{}(x_2) + , N(0, ^2) ]
where (0) is the intercept, (f{}) and (f_{}) are smooth functions for the seasonal and trend features we’re interested in, and (x_1) and (x_2) are to covariate data providing some form of time indicators for the withinyear and between year times. We can knock off the distributional assumptions and the intercept and this would be very close to the formula we need to stick into a call to gam()
from the mgcv package. In pseudo code we’d have something like
> mod < gam(y ~ s(x1) + s(x2), data = foo)
Before we can begin modelling though, we need to identify the data we’ll use for (x_1) and (x_2). I tend to the date of observation converted to a numeric variable for my between year data, (x_2), if the observation dates can easily be represented in R’s Date
class. This class counts the number of days from an epoch, Jan 1st, 1970, with negative values indicating days before this date. Seeing as we’ll probably need a nicely formatted axis for any plots we do and it is easy to convert the Date
object into a numeric (integer), this will do nicely. One thing to point out is that the numeric representation can get into some large values which might affect the stability of the model fitting; in such cases you can just divide this number by 100 or 1000 or some such value as this time value is only used to indicate relative position in time of the observations.
For the withinyear or seasonal time variable you could use the month of observation as a decimal value, which is particularly useful if you only have monthly or less frequent data. For more frequent observations I use the day of the year as my time variable. This information is also easily derived from a Date
variable using the “%j”
date format.
Data preparation
Having identified what data we’ll use, we can get to some analysis. In this post I’m going to use data from the Central England Temperature (CET) time series, one of the longest such records available. The CET data are available for daily observations, and the methods I describe here will certainly handle such data, but to save computing time and memory (you’ll need quite a big chunk of RAM to fit a gam()
to the daily series) I’m just going to use the monthly data series.
The CET data are available from the UK Met Office website and do require a little massaging to get them into a format appropriate for our use
> CET < url("http://www.metoffice.gov.uk/hadobs/hadcet/cetml1659on.dat")
> writeLines(readLines(CET, n = 10))
MONTHLY MEAN CENTRAL ENGLAND TEMPERATURE (DEGREES C)
16591973 MANLEY (Q.J.R.METEOROL.SOC., 1974)
1974ON PARKER ET AL. (INT.J.CLIM., 1992)
PARKER AND HORTON (INT.J.CLIM., 2005)
JAN FEB MAR APR MAY JUN JUL AUG SEP OCT NOV DEC YEAR
1659 3.0 4.0 6.0 7.0 11.0 13.0 16.0 16.0 13.0 10.0 5.0 2.0 8.83
1660 0.0 4.0 6.0 9.0 11.0 14.0 15.0 16.0 13.0 10.0 6.0 5.0 9.08
1661 5.0 5.0 6.0 8.0 11.0 14.0 15.0 15.0 13.0 11.0 8.0 6.0 9.75
There are 6 lines of header info and then the data are in a matrix with rows representing the year and the columns the months, with one extra column containing the derived annual mean temperature. Missing values are also indicated by either a 99.99
or 99.9
, which we’ll need to take account of. To read the data in and partly process it I use
> cet < read.table(CET, sep = "", skip = 6, header = TRUE,
+ fill = TRUE, na.string = c(99.99, 99.9))
> names(cet) < c(month.abb, "Annual")
> ## remove last row of incomplete data
> cet < cet[nrow(cet), ]
> ## get rid of the annual too  store for plotting
> rn < as.numeric(rownames(cet))
> Years < rn[1]:rn[length(rn)]
> annCET < data.frame(Temperature = cet[, ncol(cet)],
+ Year = Years)
> cet < cet[, ncol(cet)]
I used fill = TRUE
because the final row of the file contains values for the current year, which may be incomplete. I throw this year of data away as it makes the processing easier later but that’s me just being lazy! What I end up with at this point is a data frame looking like this
Jan Feb Mar Apr May Jun Jul Aug Sep Oct Nov Dec
1659 3 4 6 7 11 13 16 16 13 10 5 2
1660 0 4 6 9 11 14 15 16 13 10 6 5
1661 5 5 6 8 11 14 15 15 13 11 8 6
1662 5 6 6 8 11 15 15 15 13 11 6 3
1663 1 1 5 7 10 14 15 15 13 10 7 5
1664 4 5 5 8 11 15 16 16 13 9 6 4
For use in gam()
we need the data in long format, with variables for the temperature, and the two time variables. We also need to create some dates. As these are monthly data, I fake a day by setting it to the 15th of the month.
> ## stack the data
> cet < stack(cet)[,2:1]
> names(cet) < c("Month","Temperature")
> ## add in Year and nMonth for numeric month and a proper Date class
> cet < transform(cet, Year = (Year < rep(Years, times = 12)),
+ nMonth = rep(1:12, each = length(Years)),
+ Date = as.Date(paste(Year, Month, "15", sep = ""),
+ format = "%Y%b%d"))
> ## sort into temporal order
> cet < cet[with(cet, order(Date)), ]
>
> ## Add in a Time variable
> cet < transform(cet, Time = as.numeric(Date) / 1000)
The first line stacks the columns of the data frame creating a 2column data frame containing the month identifier and the temperature data respectively. After adding some names to the data frame, I add

a
Year
variable by repeating the rownames of thecet
data frame 12 times, once per month, 
a numeric month variable
nMonth
by repeating the values1:12
as many times as there are years in the data set, which will be used for the withinyear or seasonal variable, and 
a
Date
variable concocted from theYear
andMonth
data.
The code is a bit tricky as I create a local Year
variable whilst assigning the Year
variable of the transformed cet
data frame (spot the assignment in the first line of the call to transform()
).
Next I make sure the data are in the correct temporal order; this is useful for plotting only. Finally, a Time
variable is created which we’ll use for the trend or betweenyear variable, which I scale by 1000 as discussed above. Once this is done, the data look like this
> head(cet)
> str(cet)
Month Temperature Year nMonth Date Time
1 Jan 3 1659 1 16590115 113.6
356 Feb 4 1659 2 16590215 113.5
711 Mar 6 1659 3 16590315 113.5
1066 Apr 7 1659 4 16590415 113.5
1421 May 11 1659 5 16590515 113.5
1776 Jun 13 1659 6 16590615 113.4
'data.frame': 4260 obs. of 6 variables:
$ Month : Factor w/ 12 levels "Apr","Aug","Dec",..: 5 4 8 1 9 7 6 2 12 11 ...
$ Temperature: num 3 4 6 7 11 13 16 16 13 10 ...
$ Year : int 1659 1659 1659 1659 1659 1659 1659 1659 1659 1659 ...
$ nMonth : int 1 2 3 4 5 6 7 8 9 10 ...
$ Date : Date, format: "16590115" "16590215" ...
$ Time : num 114 114 114 113 113 ...
and we are good to go. First though, the obligatory time series plot (of the annual data only)
> ylab < expression(Temperature ~ (degree*C))
> plot(Temperature ~ Year, data = annCET, type = "l",
+ ylab = ylab, main = "CET")
If you plot the full data, you get a mess^{1} — try it if you want
> plot(Temperature ~ Date, data = cet, type = "l",
+ ylab = ylab)
There looks to be some trend in the data and we expect seasonal variation in temperature, as despite plenty of evidence to the contrary, the UK does have a summer and it can snow from time to time.
A model with uncorrelated errors
To start our trip down the modelling rabbit hole, I fit an obviously wrong model where I assume the observations are all independent. This serves two purposes;

We get to run the data through the modelling function
gamm()
so we see how this goes and can spot errors before we set the thing off with estimating the smooths and the correlation matrix (which can take a lot of time with big data sets), and  It is worth hammering home the point that you can easily fit noise in the data if you forget to tell the software that the data aren’t independent observations!
Load mgcv and fit the naive model
> require("mgcv")
> m < gamm(Temperature ~ s(nMonth, bs = "cc", k = 12) + s(Time),
+ data = cet)
which takes about a second on my 2013 Intel Xeon.
The important thing to note there is the extra arguments passed to the first s()
term in the model. k
specifies the dimensions of the basis used for the spline. Here I set it to the maximum possible for nMonth
, which is 12 the number of unique values. bs
allows you to specify the basis type for the smooth term; “cc”
indicates a cyclic cubic spline, which we want for the seasonal term as there should be no discontinuity between January and December.
Cyclic cubic spline basis
So what’s a cyclic cubic spline? Well, first let’s look at the standard cyclic cubic spline basis
The lefthand plot shows a single basis function centred on a knot at 0.5. The xaxis here is arbitrary, but it would represent the observed covariate data, (x_2) say. The vertical dashed lines show the locations of the 5 interior knots plus the two boundary knots. The more knots we have the more complex the fitted spline can be. A cubic spline basis function for a given knot takes a value 1 at its knot location and a value of 0 at all other knots. The figure shows only a single basis function, but there are equivalent functions positioned at each of the other 6 knots.
When we fit the model, mgcv is estimating coefficvients for each of these basis functions. The final spline is given by a weighted sum of the basis functions with the estimated coefficients used as the weights. This is illustrated in the righthand figure, where I have arbitrarily chosen some coefficient values, which scale each basis function. The “fitted” spline is shown in the thick black line. The values of this spline are determined by adding up the values of all the basis functions under each point on spline.
A key point to note here is that there is a large discontinuity in the value taken by the spline (the thick black line) at the ends of the data, at each end of the xaxis on the plot. If x
represented something like day of year, or month, that discontinuity would be a bad thing if, as is the case here, the variable of interest (temperature) behaved cyclically.
This is where the cyclic cubic spline basis comes in. This basis has an additional constraint, which states that there should be no discontinuity at the end points of the spline. In other words, we force the ends of the cyclic spline to join up. This is illustrated below
This time, to make it clearer, the left hand panel shows a cubic cyclic spline basis function located at a x
= 0.167. If you were to wrap the xaxis into a loop by joining the end points the basis function would meet nicely and smoothly at the join. The basis function still takes a value of 1 at its knot and 0 at the other knots, just as before, and there is a matching basis function for each of the knots, they’re just not shown in this panel.
The right hand panel shows how the “fitted” spline is derived as a weighted sum of the basis functions underneath any point on the spline. Because the basis functions all smoothly join at the end points of x
, so does the fitted cyclic cubic spline.
Similar constraints can be put on other spline types. mgcv has cyclic p splines as well as the cyclic cubic splines I showed here for example.
Back to our model
With that out of the way we can look at our model fit
> summary(m$gam)
Family: gaussian
Link function: identity
Formula:
Temperature ~ s(nMonth, bs = "cc", k = 12) + s(Time)
Parametric coefficients:
Estimate Std. Error t value Pr(>t)
(Intercept) 9.2226 0.0212 435 <2e16 ***

Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
Approximate significance of smooth terms:
edf Ref.df F pvalue
s(nMonth) 9.71 10.00 4664.1 <2e16 ***
s(Time) 8.15 8.15 28.8 <2e16 ***

Signif. codes: 0 '***' 0.001 '**' 0.01 '*' 0.05 '.' 0.1 ' ' 1
Rsq.(adj) = 0.917 Scale est. = 1.9117 n = 4260
which looks fine but is totally spurious because we didn’t account for the dependence in the data. Plotting the model terms is illustrative of what can go wrong if you forget to do this
> layout(matrix(1:2, ncol = 2))
> plot(m$gam, scale = 0)
> layout(1)
The figure shows the two splines; the one on the left is the seasonal term, the cyclic cubic spline (note how the ends join nicely!), and the one on the right is the trend term (note how ridiculously wiggly this is!) The splines are on very different scales (scale = 0
) which illustrates the relative degrees of variation int he seasonal and trend term; there is about 11.5 degree rise in temperature over the period, but within a given year there is about 12 degrees variation in temperature, on average. Obviously, the actual data vary around these values and that is the unexplained variance.
We should look at the residuals of this model too, here using the (partial) autocorrelation function
> layout(matrix(1:2, ncol = 2))
> acf(resid(m$lme), lag.max = 36, main = "ACF")
> pacf(resid(m$lme), lag.max = 36, main = "pACF")
> layout(1)
As expected, the is substantial residual autocorrelation in the data that even the wiggly trend term couldn’t account for. The shapes of the ACF and the pACF suggest an AR(p) model might be needed…
Models with correlated errors
It looks like some loworder AR model is needed, so I fit three models; and AR(1), an AR(2), and an AR(3). I turn on verbose output and so have to reset some other things to in the ctrl
object. Note that these take about 5–6 seconds each to converge on my Xeon workstation.
> ctrl < list(niterEM = 0, msVerbose = TRUE, optimMethod="LBFGSB")
>
> ## AR(1)
> m1 < gamm(Temperature ~ s(nMonth, bs = "cc", k = 12) + s(Time, k = 20),
+ data = cet, correlation = corARMA(form = ~ 1Year, p = 1),
+ control = ctrl)
>
> ## AR(2)
> m2 < gamm(Temperature ~ s(nMonth, bs = "cc", k = 12) + s(Time, k = 20),
+ data = cet, correlation = corARMA(form = ~ 1Year, p = 2),
+ control = ctrl)
>
> ## AR(3)
> m3 < gamm(Temperature ~ s(nMonth, bs = "cc", k = 12) + s(Time, k = 20),
+ data = cet, correlation = corARMA(form = ~ 1Year, p = 3),
+ control = ctrl)
It is important to note what the correlation
argument is doing here: corARMA(form = ~ 1Year, p = x)
means fit an ARMA process to the residuals, where p
indicates the order for the AR part of the ARMA model, and form = ~ 1Year
means that the ARMA is nested within each year. This speeds up fitting no end, but is potentially risky as we don’t consider residual variation from year to year.
We should probably do a lot more model checking, but for now, I cut to the chase and see which of the candidate models fits the data best. This is done via a generalized likelihood ratio test via the anova()
method of “lme”
objects. This is a valid comparison because the models are nested; we can go from the AR(3) to the AR(1) by setting some of the AR coefficients to 0. Technically, the models are also varying in terms of the coefficient estimates for the splines terms; we probably ought to fix those at some values whilst we choose the AR structure, but I ignore that here.
> anova(m$lme, m1$lme, m2$lme, m3$lme)
Model df AIC BIC logLik Test L.Ratio pvalue
m$lme 1 5 14941 14973 7466
m1$lme 2 6 14657 14695 7323 1 vs 2 286.35 <.0001
m2$lme 3 7 14631 14676 7309 2 vs 3 27.88 <.0001
m3$lme 4 8 14631 14682 7307 3 vs 4 2.52 0.1123
The AR(1) provides a substantial increase in fit over the naive model, and the AR(2) provides a further significant increase in the fit. There is very little improvement in moving to the AR(3) however.
Plotting the AR(2) model terms shows how overfitted the naive model with uncorrelated errors was in terms of the trend term, which is now much smoother and more in keeping with our expectations
> layout(matrix(1:2, ncol = 2))
> plot(m2$gam, scale = 0)
> layout(1)
Looking now at the normalized residuals (which take into account the covariance matrix of the residuals), we see no important or significant residual autocorrelation suggesting that the AR(2) model is sufficient and we can, to some degree, draw inference from the model.
> layout(matrix(1:2, ncol = 2))
> res < resid(m2$lme, type = "normalized")
> acf(res, lag.max = 36, main = "ACF  AR(2) errors")
> pacf(res, lag.max = 36, main = "pACF AR(2) errors")
> layout(1)
Extracting individual model terms
The fitted GAM model object contains a lot of information that can be used to interrogate the model. For the purposes of this post I’m interested in the trend terms, so I can extract information about the contributions to the fitted values of our chosen model by getting mgcv to spit out this information using predict()
and type = “terms”
. In the code below, I do this for each of the four models we’ve fitted, predicting for 200 evenlyspaced values over the range of the date. Note want
picks out the 200 values from the observed data as these are evenly spaced. For more complex data you may need to be a bit more clever about how you choose these values.
> want < seq(1, nrow(cet), length.out = 200)
> pdat < with(cet,
+ data.frame(Time = Time[want], Date = Date[want],
+ nMonth = nMonth[want]))
>
> ## predict trend contributions
> p < predict(m$gam, newdata = pdat, type = "terms", se.fit = TRUE)
> p1 < predict(m1$gam, newdata = pdat, type = "terms", se.fit = TRUE)
> p2 < predict(m2$gam, newdata = pdat, type = "terms", se.fit = TRUE)
> p3 < predict(m3$gam, newdata = pdat, type = "terms", se.fit = TRUE)
>
> ## combine with the predictions data, including fitted and SEs
> pdat < transform(pdat,
+ p = p$fit[,2], se = p$se.fit[,2],
+ p1 = p1$fit[,2], se1 = p1$se.fit[,2],
+ p2 = p2$fit[,2], se1 = p2$se.fit[,2],
+ p3 = p3$fit[,2], se1 = p3$se.fit[,2])
Note that it doesn’t matter what months get select in the 200 values as the month effect is handle by the other spline term; here we get the contribution for the trend which is based on the Time
variable only. This would need to be different if you allowed the seasonal and trend splines to interact; I’ll look at this is a future post at some point.
Now I am ready to plot the estimated trends for the four models fitted
> op < par(mar = c(5,4,2,2) + 0.1)
> ylim < with(pdat, range(p, p1, p2, p3))
> ylim[1] < floor(ylim[1])
> ylim[2] < ceiling(ylim[2])
> ylab < expression(Temperature ~ (degree*C ~ centred))
> plot(Temperature  mean(Temperature) ~ Date, data = cet, type = "n",
+ ylab = ylab, ylim = ylim)
> lines(p ~ Date, data = pdat, col = "black")
> lines(p1 ~ Date, data = pdat, col = "red")
> lines(p2 ~ Date, data = pdat, col = "blue")
> lines(p3 ~ Date, data = pdat, col = "forestgreen", lwd = 1)
> legend("topleft",
+ legend = c("Uncorrelated Errors", paste0("AR(", 1:3, ") Errors")),
+ bty = "n", col = c("black","red","blue","forestgreen"),
+ lty = 1, lwd = c(1,1,1))
> par(op)
This plot nicely illustrates the reduction in wiggliness of the estimated trend in the AR(2) and AR(3) models, and how similar the two higherorder AR models are in terms of their trend estimates.
I’ll leave things at this point; in the next post I’ll look at how we can look at where the estimated trend is changing in a statistically significant fashion by interrogating the fitted GAM in deeper and more devious ways.
Disclaimer
Don’t over interpret the model fits here; they were done to illustrate how to get mgcv to fit models to seasonal data. If you were doing this in anger for a real analysis then we’d want to look in a lot more detail at unmodelled features such as changes in the seasonal temperature with the trend and do a lot more in terms of model diagnostics. Such things are beyond the scope of this particular post, but I will pick some of these issues up in later postings as time permits.

It’s not a mess really; the problem is that there are so many years of data that the years are all squished up tight and coupled with the magnitude of the seasonal variation leads to an irregular black band obscuring everything.↩
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