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FERNANDO VILLATE1*, GUILLERMO ARAVENA1, ARANTZA IRIARTE1 AND IBON URIARTE2
1
LABORATORY OF ECOLOGY, DEPARTMENT OF PLANT BIOLOGY AND ECOLOGY, FACULTY OF SCIENCE AND TECHNOLOGY, UNIVERSITY OF THE BASQUE COUNTRY,
644, 48008 BILBAO, SPAIN AND 2LABORATORY OF ECOLOGY, DEPARTMENT OF PLANT BIOLOGY AND ECOLOGY, FACULTY OF PHARMACY, UNIVERSITY OF
PO BOX
THE BASQUE COUNTRY, PASEO DE LA UNIVERSIDAD
7, 01006 VITORIA-GASTEIZ, SPAIN
*CORRESPONDING AUTHOR: fernando.villate@ehu.es
Received March 10, 2008; accepted in principle May 12, 2008; accepted for publication May 20, 2008; published online May 24, 2008
Corresponding editor: William Li
The relationships between chlorophyll a concentration and environmental (climatic and associated
hydrographical) factors were investigated in the estuary of Urdaibai (Bay of Biscay) in different
salinity zones of the euhaline region, using time-series for the period 1997– 2006. Transfer function (TF) models were used on quarterly data (3 month mean values) to establish possible
relationships between time-series. In the non-nutrient limited waters with salinities of 30 and
33 PSU, a chain of effects from the North Atlantic Oscillation (NAO) to chlorophyll a was established, where air temperature followed inversely the NAO index, water temperature followed air
temperature and chlorophyll a followed water temperature. Each of the steps occurred with a lag of
0 (within the 3 month period); however, the effect from NAO to chlorophyll a showed a lag of 1
(a mean of 3 months delay). Consistent with this result, annual mean chlorophyll a biomass in
the 30 and 33 PSU salinity zones showed a significant positive relationship with annual mean
water temperature and a significant negative relationship with the 12 month mean NAO index
from October of the previous year to September. In the 35 PSU salinity zone, no significant
relationship between chlorophyll a and NAO or water temperature was observed. It is suggested
that nutrient limitation distorts the effect of temperature on phytoplankton biomass enhancement in
the outer estuary (35 PSU salinity zone).
I N T RO D U C T I O N
It is well known that meteorological factors affect phytoplankton dynamics (Smayda et al., 2004). Much of this
information has been obtained from studies on a
seasonal time scale and the lack of time-series data of
phytoplankton has precluded to a large extent the investigation of climate forcing at inter-annual time scales
(Edwards et al., 2001). However, in a possible global
warming scenario, knowledge about phytoplankton
responses to meteorological variations at longer time
scales is increasingly important. Traditionally, emphasis
has been placed on the effects of locally measured
meteorological factors, but more recently investigations
have
focused
on
the
influence
of
the
sub-continental scale (Miller and Harding, 2007) or
large-scale climate patterns (teleconnection patterns)
such as the North Atlantic Oscillation (NAO) and the El
Niño Southern Oscillation (Stenseth et al., 2003). In the
North Atlantic, the NAO has been shown to affect phytoplankton biomass and composition mainly in shelf
doi:10.1093/plankt/fbn056, available online at www.plankt.oxfordjournals.org
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Axial variability in the relationship of
chlorophyll a with climatic factors and
the North Atlantic Oscillation in a
Basque coast estuary, Bay of Biscay
(1997–2006)
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NAO index is expressed in a strong enough manner for
phytoplankton to show a significant response to it in the
estuary of Urdaibai; (iii) the axial variability in the
response of chlorophyll a biomass to climate forcing in
this estuary. As a general aim, we have also tried to contribute to fill a geographic gap in the knowledge of the
NAO effects on phytoplankton in the North Atlantic.
To achieve these goals, the relationships between timeseries of chlorophyll a concentration (taken as an indicator of phytoplankton biomass) and water temperature
from different salinity zones of the estuary of Urdaibai,
time-series of meteorological variables and available
NAO index series have been analysed using transfer
function (TF) modelling as the main statistical tool.
TF models are claimed to be particularly useful to
analyse the response of a time-series to the past and
present values of other related time-series and have
been successfully used, among other methods, when
analysing the relationships between the time-series of
water quality variables, climate, hydrography and plankton (Bhangu and Whitfield, 1997; Lehmann and Rode,
2001; Hänninen et al., 2003; Vuorinen et al., 2003;
Lehman, 2004).
METHOD
Study area
The estuary of Urdaibai (438220 N, 28430 W), also called
the estuary of Mundaka, is located on the Basque coast,
in the inner Bay of Biscay, within the middle latitudes of
the eastern North Atlantic (Fig. 1). This area is influenced by the Gulf Stream and the atmospheric westerlies in the middle and upper troposphere; and the
climate is temperate-oceanic with moderate winters and
warm summers (Usabiaga et al., 2004).
This estuary is a relatively short (12.5 km) and
shallow (mean depth of 3 m) meso-macrotidal system.
The central channel is bordered by salt marshes at its
upper and middle reaches and by relatively extensive
intertidal flats (mainly sandy) and sandy beaches at its
lower reaches. The watershed area is relatively small in
relation to the estuarine basin, and river inputs are
usually low in relation to the tidal prism. In consequence, most of the estuary is marine-dominated,
with high salinity waters in the outer half and a stronger
axial gradient of salinity towards the head, where it
receives most of the freshwater inputs from its main
tributary, i.e. the Oka river. In the upper reaches, the
estuary receives large amounts of nutrients and organic
matter from a waste water treatment plant (Franco et al.,
2004). In the outer zone, tidal flushing is high, to the
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seas (Barton et al., 2003; Leterme et al., 2005). The
nature of the relationship between NAO and phytoplankton, however, is claimed to vary within the North
Atlantic, and this is partly due to the variety of environmental factors that the NAO can affect, e.g. temperature, water column stratification, currents and associated
nutrients (Richardson and Schoeman, 2004; Leterme
et al., 2005), and partly due to the geographic variability
in the climatic expression (temperature and precipitation) of the NAO (Visbeck et al., 2001).
Positive phases of the NAO index result in stronger
westerly winds, increased precipitation and temperatures
over northern Europe and south-eastern USA, but
decreased precipitation and temperatures over northern
Africa. Roughly, the opposite conditions correspond to
negative phases of the NAO index (Visbeck et al., 2001).
The Basque coast (northern Iberian peninsula) is
located roughly at the border of these two climatically
distinct regions, i.e. northern/central Europe and northern Africa. Previous studies have not shown a clear-cut
picture of how the NAO relates to climate or to water
temperature in the Basque coastal region (inner Bay of
Biscay). While Saenz et al. (Saenz et al., 2001a) found no
significant correlation between NAO and surface air
temperature over the northern Iberian Peninsula,
Garcı́a-Soto et al. (Garcı́a-Soto et al., 2002) showed
winter sea surface temperature to be negatively correlated to NAO in the Cantabrian Sea (Bay of Biscay).
Regarding possible effects of the NAO on phytoplankton, Beaugrand et al. (Beaugrand et al., 2000)
showed no significant relationship between phytoplankton and the NAO in shelf edge and deep oceanic waters
of the Bay of Biscay. However, the relationship has not
been tested in estuarine waters. Being at the land – sea
interface, many estuaries receive large amounts of nutrients that make them (or some zones within them)
highly productive systems. The response of phytoplankton to temperature can be affected by nutrient availability (Rhee and Gotham, 1981; Geider et al., 1997). In
many estuaries, strong spatial variations in nutrient concentrations can be found from the intermediate/inner
to the outer zones and they can be ideal systems to test
the hypothesis that phytoplankton response to climate is
different in nutrient-replete and nutrient-limited waters.
The estuary of Urdaibai, located on the Basque coast
and draining into the Bay of Biscay, shows an axial gradient in nutrient concentrations, from the outer zone,
which is nutrient-limited in summer, to the nutrient-rich
intermediate and inner zones (Iriarte et al., 1996).
In view of these considerations, we set out to investigate the following: (i) the relationship between the NAO
index and the local climate on the Basque coast and its
possible effect on water temperature; (ii) whether the
30
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AXIAL VARIABILITY IN THE RELATIONSHIP OF CHLOROPHYLL A
Chlorophyll a values (mg L21) were transformed to log
(x + 1) values to achieve homogeneity of variance.
Air temperature, number of hours of
sunshine, rainfall, NAO index and
river flow data sets
Statistical analyses
Fig. 1. Map of the study area showing the location of the sampling
zones.
extent that waters of salinities .34 PSU are flushed out
of the estuary with each tidal cycle (Villate et al., 1989).
The outer half of the estuary remains well mixed most
of the time, and the inner half is partially stratified.
Chlorophyll a and water temperature
data sets
Monthly sampling was conducted from 1997 to 2006.
Sampling was carried out during the last week of each
month at high tide in the euhaline (salinity 30 PSU)
region of the estuary. This estuarine region was chosen
because river flow is relatively low in relation to the
tidal prism and the euhaline waters constitute the main
water body within the estuary at high tide (see Fig. 1 for
location). Water samples were collected for chlorophyll a
analysis from below the halocline (ca. mid depth) at
three selected salinities: 30, 33 and 35 PSU. In the
30 PSU salinity zone, sampling commenced in 1999. At
each sampling point, vertical profiles of temperature
and salinity were obtained using WTW water quality
meters. Chlorophyll a was measured spectrophotometrically according to the monochromatic method
with acidification (Jeffrey and Mantoura, 1997).
Occasional missing data in the time-series were interpolated using the Tramo-Seats package incorporated in
the Demetra 2.0 interface, according to the methodology described by Gómez and Maravall (Gómez and
Maravall, 1994) and Gómez et al. (Gómez et al., 1999).
The method used for interpolation was the additive
outlier (AO) approach with correction in the determinantal term of the likelihood (Gómez and Maravall,
1994). Given that the number of missing observations
was not high (10%), this method gave similar results
to the skipping approach, and the former was used following suggestions by Gómez and Maravall (Gómez
and Maravall, 1994).
To get a better picture of inter-annual variations, the
seasonal component of air and water temperature, sunshine, rainfall, river flow and chlorophyll a series was
removed by calculating the difference between the
monthly value and the average for all years for each
month divided by the standard deviation. This is a
common procedure to deseasonalize time-series (e.g.
Lehman, 2004). To better visualize inter-annual variations in the deseasonalized series, data were fitted
using moving average curves (6 month period).
To assess the relationships between NAO, climatic
factors and chlorophyll a time-series, TF models were
fitted using SAS 9.1 software, SAS Institute Inc. We used
the TF methodology of Box and Jenkins (Box and
Jenkins, 1976). Since, in most studies, seasonal NAO
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Monthly mean air temperature, monthly accumulated
rainfall and monthly number of cloudless hours
were provided by the Spanish National Institute of
Meteorology (Sondika) and the Provincial Council of
Bizkaia (Muxika). The average values between data
measured at the meteorological stations of Sondika and
Muxika were taken. The number of hours of sunshine
was only available from Sondika. Oka river flow data
were provided by the Provincial Council of Bizkaia and
correspond to the Muxika gauging station.
Monthly NAO indices based on the difference in sea
level pressure between Ponta Delgada, Azores (388N,
268W), and Akureyri, Iceland (668N, 188W), calculated
by Rogers (Rogers, 1984) were taken from http://
polarmet.mps.ohio-state.edu/NAO/.
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indices are used, for the TF modelling quarterly mean
(January–February–March, April–May–June, July–
August–September and October–November–December)
values were used for all variables, as has been done in
other similar studies (e.g. Hänninen et al, 2003).
The linear TF model can be written in the general
form:
uq ðBÞ
vs ðBÞ
ÞXtb þ ð
Þat
dr ðBÞ
fp ðBÞ
where Yt is the output series (the dependent variable);
Xt the input series (the independent variable); C the
constant term, vs(B) and dr(B) are the polynomial delay
functions; B represents the backward shift operator and
b is the delay time before Xt begins to influence Yt . The
parameter fp is the autoregressive (AR) operator in
non-seasonal series, and uq represents the moving
average operator (MA). Here, at corresponds to the
errors that are independently and identically distributed
with normal distribution.
In order to take care of non-stationary mean and variance, the response variable (output) and the explanatory variable (input) must, if necessary, be appropriately
transformed. In the present work, where most series
have a strong seasonal behaviour, a difference of order
4 (1 year) has been applied.
According to the Box and Jenkins (1976) methodology, TF modelling is a three-step procedure. In the
first step, the cross-correlation function (CCF) is used to
identify the model. For the CCF to be meaningful, the
input and output series must be filtered with a prewhitened model in order to reduce the residuals to white
noise. The filter used for the output series must be the
filter derived from the univariate analysis of the input
variable. The use of prewhitened series to calculate the
CCF is fundamental to reveal the existence of underlying relationships apart from the seasonal behaviour of
the data. In the second step, the estimation of the
model is carried out using the maximum likelihood
methods and, finally, the diagnosis of the model is done
using standard test statistics such as the modified
Ljung-Box test (Stoffer and Toloi, 1992). For a more
detailed description of the methodology, see Box and
Jenkins (Box and Jenkins, 1976).
The relationship between variables was also tested
using parametric regression analysis. Linear regressions
of chlorophyll a concentration on water temperature and
NAO index were performed by the method of “least
squares” using SPSS 15.0 software on normalized data.
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R E S U LT S
Data showed a longitudinal gradient in chlorophyll a
concentration in the euhaline region of the Urdaibai
estuary (Figs 2–4), decreasing from the inner 30 PSU
salinity zone (peak values ca. 25 mg L21) to the intermediate 33 PSU salinity zone (peak values ca. 12 mg
L21) and to the outer 35 PSU salinity zone (peak values
ca. 4 mg L21). The seasonal pattern of chlorophyll a
concentration showed axial variations. In the 30 and
33 PSU salinity zones, it was a unimodal cycle with
annual maxima in summer, whereas in the outer 35
salinity zone, chlorophyll a exhibited a bimodal cycle,
with a spring maximum and a secondary peak in late
summer–early autumn (Fig. 5). The inter-annual variations in the deseasonalized time-series (Figs. 2–4 and 6)
showed great similarities for chlorophyll a at salinities of
30 and 33 PSU, water temperature at the three salinities
tested and air temperature. The trend for the NAO
index was roughly opposite (Fig. 6). The pattern of variation of other meteorological and hydrological variables
studied (rainfall, number of cloudless hours and river
flow) did not show a correspondence with those of chlorophyll a, temperature or NAO index (Fig. 6). In the
series, two years can be highlighted for their meteorological features. In 2002, the NAO index was dominantly
positive, whereas that of 2003 was mainly negative.
Accordingly, 2002 was cooler than other years and
2003 was the warmest of the series. Chlorophyll a concentrations were lower than usual at salinities of 30 and
33 PSU during 2002 and were high in 2003.
After this graphical analysis of the series, TF models
were performed to test if there are statistically significant
relationships between chlorophyll a concentration,
environmental factors (air temperature, number of
cloudless hours, rainfall, river flow and water temperature) and NAO index. Only results of the TF models
Fig. 2. Time-series of chlorophyll a and water temperature in the
30 PSU salinity zone (left). Deseasonalized time-series of chlorophyll a
and water temperature in the 30 PSU salinity zone (thin lines) and
their corresponding moving averages (thick lines) (right).
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Yt ¼ C þ ð
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Fig. 4. Time-series of chlorophyll a and water temperature in the
35 PSU salinity zone (left). Deseasonalized time-series of chlorophyll a
and water temperature in the 35 PSU salinity zone (thin lines) and
their corresponding moving averages (thick lines) (right).
that showed significant (P , 0.05) correlations between
time-series are shown in Table I, with the exception of
the relationship between NAO index and chlorophyll a
for the 30 PSU salinity zone, which was just below the
significance level (P = 0.057). The corresponding CCFs
have been plotted in Figs 7 and 8, in order to show the
lag time of the response of one variable to another.
From the TF modelling results, we can see that chlorophyll a concentration showed a positive response to water
temperature at salinities of 30 PSU (t = 3.21, P = 0.003)
and 33 PSU (t = 3.82, P , 0.001), but not at salinities of
35 PSU (Table I). In addition, a low quarterly NAO index
was related with increased air temperature and this, in
turn, was directly connected with water temperature at all
the salinities tested (Table I). All these significant relationships showed a lag of 0 (i.e. effect within the same
quarter) (Figs 7 and 8). This means that in the estuary of
Urdaibai at salinities of 30 and 33 PSU, a chain of effects
could be observed from NAO to air temperature to water
Fig. 6. Time-series of monthly NAO index, surface air temperature,
number of cloudless hours, rainfall and river flow (left). Deseasonalized
time-series of surface air temperature, number of cloudless hours,
rainfall and river flow (thin lines) and their corresponding moving
averages (thick lines) (right). The NAO index series shows no seasonality
and the thin line corresponds to the raw series.
temperature and to chlorophyll a. TF modelling also
revealed a negative relationship between chlorophyll a
concentration and the NAO index (t = 24.06, P , 0.001)
in waters of salinity of 33 PSU with a lag time of 1, i.e.
chlorophyll a increases were detected in the following
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Fig. 3. Time-series of chlorophyll a and water temperature in the
33 PSU salinity zone (left). Deseasonalized time-series of chlorophyll a
and water temperature in the 33 PSU salinity zone (thin lines) and
their corresponding moving averages (thick lines) (right).
Fig. 5. Seasonal pattern of chlorophyll a in the 30 (dashed), 33 (solid)
and 35 (dotted) PSU salinity waters. To calculate the deviations, the
annual median was removed from each monthly value, leaving a
time-series of deviations for each month from the annual median for
that year. The median seasonal pattern was found by using the
median of each monthly deviation for all years.
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Table I: Transfer function model results,
showing the relationships between time-series
Variable
Lag
b
t
P-value
NAO versus air temperature
NAO
0
20.795 24.82 ,0.001
Air temperature versus water
temperature salinity 30
AR1,1
Air temp
4
0
20.699 24.60 ,0.001
0.279
2.18
0.039
Air temperature versus water
temperature, salinity 33
MA1,1
Air temp
4
0
Air temperature versus water
temperature, salinity 35
AR1,1
Air temp
4
0
Water temperature versus
chlorophyll a, salinity 30
MA1,1 4
Wat temp 0
Water temperature versus
chlorophyll a, salinity 33
AR1,1
4
Wat temp 0
0.581
0.370
4.01 ,0.001
3.35
0.002
0.834
0.113
5.99 ,0.001
3.21
0.004
20.690 24.76 ,0.001
0.102
3.82
0.001
NAO versus chlorophyll a,
salinity 30
MA1,1
NAO
4
1
0.757
4.83 ,0.001
20.078 22.01
0.057
NAO versus chlorophyll a,
salinity 33
NAO
1
20.089 24.06
0.001
All the time-series contain quarterly mean values for the period 1997 –
2005, except those of water temperature and chlorophyll a at 30 PSU
salinity, which extend from 1999 to 2005 (b is the parameter estimate, t
the statistic, MA1,1 the moving average term and AR1,1 the AR term).
quarter (Table I and Fig. 8). Chlorophyll a and NAO
index in waters of salinity of 30 PSU were only weakly
correlated according to the CCFs (Fig. 8), and the TF
model regression was nearly significant (Table I).
Regression analyses (Fig. 9) showed annual mean
chlorophyll a concentration to be positively and significantly related to annual mean water temperature at salinities of 30 PSU (P = 0.013) and 33 PSU (P = 0.003)
and to be negatively and significantly related to the
NAO index averaged from October of the previous year
to September also at salinities of 30 PSU (P = 0.048)
and 33 PSU (P , 0.001). The NAO index that we used
reflects the lagged effect of the NAO on chlorophyll a
shown by the TF models.
DISCUSSION
The NAO is claimed to have a roughly opposite climate
expression (surface air temperature and precipitation) in
northern/central Europe and northern Africa (Visbeck
et al., 2001). The Basque coast seems to be located in a
transition zone between the two. Previous studies conducted in the area have shown contradictory results.
Saenz et al. (Saenz et al., 2001a) reported no correlation
between a winter NAO index and surface air temperature in the northern Iberian Peninsula, but this study
was conducted over a broader geographical area, and
Fig. 7. CCF to lag 5 for the prewhitened time-series (air temperature
versus NAO index, water temperature versus air temperature at the
30, 33 and 35 PSU salinity waters). Standard error limits are shown as
broken lines. The TF analysis was performed grouping data in
quarterly means (see text for further details).
temperature variations from inland to coastal sites
within the northern Iberian Peninsula can be significant, due, among others, to Föehn effects (Saenz et al.,
2001a). In contrast, Garcı́a-Soto et al. (Garcı́a-Soto et al.,
2002) showed winter water warming during marked
Navidad years to be negatively correlated with a
November– December NAO index. Our TF modelling
results have shown that on the Basque coast, in relation
to temperature, the NAO has a Mediterranean-like
expression, where positive phases of the NAO result in
decreased surface air temperatures and these, in turn,
result in decreased water temperatures. The NAO index,
however, showed no significant correlation with precipitation, which is in accordance with results from other
studies for the north-eastern area of the Iberian
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20.576 23.56
0.001
0.333
3.70 ,0.001
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Fig. 9. Relationship between annual mean chlorophyll a
concentration and annual mean water temperature (top). Relationship
between annual mean chlorophyll a concentration and NAO index
averaged from October of the previous year to September (bottom).
Grey, dark and open circles represent the 30, 33 and 35 PSU salinity
waters, respectively.
Peninsula, including both the Cantabrian and the
Mediterranean coasts (Rodó et al., 1997; Saenz et al.,
2001b). The time-series analysed in our study only covers
a decade; however, these results hold when tested for a
longer (30 year) period (Aravena et al., unpublished data).
According to the TF results from the present work,
the NAO effect on water temperature was strong enough
to affect phytoplankton biomass at salinities of 30 and
33 PSU and this was best shown as a chain of effects
from NAO to air temperature, to water temperature and
to chlorophyll a, although it was also evident when we
tested the relationship between the time-series of the
NAO and chlorophyll a in the 33 PSU waters, the latter
showing a lag that was not apparent in the sequential
relationships within the chain. The almost significant TF
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Fig. 8. As in Fig. 6 for chlorophyll a versus water temperature and
chlorophyll a versus NAO index in the 30 and 33 PSU salinity waters.
model (P = 0.057) of NAO versus chlorophyll a obtained
for waters of 30 PSU of salinity was likely due to the
smaller number of data points available for this salinity
zone. Consistent with the TF results, regression analysis
showed that annual mean chlorophyll a concentration at
salinities of 30 and 33 PSU was positively correlated
with annual mean water temperature and negatively
with the NAO index averaged from October of the
previous year to September.
Significant relationships between the NAO and phytoplankton biomass have been reported in different
areas across the North Atlantic, particularly in shelf
waters (Barton et al., 2003; Leterme et al., 2005).
However, the relationship between the NAO and phytoplankton biomass is not always negative as in some
zones within the estuary of Urdaibai, and appears to be
site-specific. The complexity of the NAO – phytoplankton relationship is often explained in terms of the
variety of indirect impacts that the NAO can have on
the physico-chemical characteristics of seawater, via
temperature, water column mixing and currents, and
associated changes in nutrients (Leterme et al., 2005).
For example, Richardson and Schoeman (2004)
found that in the Northeast Atlantic, in turbulent,
nutrient-rich, cool waters, warming can enhance phytoplankton biomass by increasing metabolic rates and
stratification, whereas in stratified-nutrient-poor warm
waters warming can cause phytoplankton biomass to
decrease because it enhances existing stratification and
limits access to nutrients. In agreement with this
finding, Edwards et al. (Edwards et al., 2001) found that
NAO shows a positive correlation with dinoflagellates,
but negative with diatoms. The complexity of the
relationship between the NAO and chlorophyll a can also
be seen in estuaries and bays. Thus, Belgrano et al.
(Belgrano et al., 1999) found a positive correlation
between winter NAO and spring phytoplankton
biomass/primary production in the Gullmar Fjord
(Sweden), which they explained in terms of variations in
water circulation caused by the NAO. For Narragansett
Bay, however, Smayda et al. (Smayda et al., 2004)
reported a negative relationship between annual mean
NAO and annual mean chlorophyll a concentration,
which they attributed to temperature-dependent changes
in grazing. Also, in Narragansett Bay, in addition to
effects caused by temperature changes, the NAO effect is
also likely related to modifications in hydrography.
In the estuary of Urdaibai, water circulation and
mixing is governed by tides and river discharge.
Therefore, it is unlikely that the increase in phytoplankton biomass following increases in temperature is
related to modifications of currents caused by NAO. We
hypothesize that direct temperature effects causing
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warmest period of the year (Ruiz et al., 1998).
Temperature and nutrient availability have a combined
effect on phytoplankton growth (Rhee and Gotham,
1981; Geider et al., 1997). We suggest that in the outer
estuary of Urdaibai, nutrient limitation prevents phytoplankton biomass responding to temperature variations
in the way it does in nutrient-rich zones of the estuary.
Iron limitation has been suggested to interact with the
temperature dependence of phytoplankton growth in
the Pacific ocean (Nori et al., 2005) and resource limitation has also been shown to distort the temperature
dependence of bacterial metabolism in the oceans
(López-Urrutia and Morán, 2007). In agreement with
our findings for the 35 PSU salinity waters of the
estuary of Urdaibai, a study conducted in shelf edge
and deep oceanic waters of the Bay of Biscay showed
no significant relationship between phytoplankton and
the NAO (Beaugrand et al., 2000). We believe that in
the Urdaibai estuary, the NAO only induces significant
variations in chlorophyll a concentration in non-nutrient
limited waters, such as the intermediate and inner
zones of the estuary, where chlorophyll a peaks occur in
the warmest season. Results from the present study can
contribute to fill a geographic gap in the knowledge of
the NAO effects on phytoplankton in the North
Atlantic, and warn of the enhancement of eutrophication that could occur with global warming in nonnutrient limited estuarine waters.
AC K N OW L E D G E M E N T S
We would like to thank Dr. Berta Ibañez for assistance
with the transfer function modelling. Thanks are also
due to the Provincial Council of Bizkaia for providing
meteorological and river flow data.
FUNDING
Financial support for this research was provided predominantly by the UNESCO Chair on “Sustainable
Development and Environmental Education” (UNESCO
03/04), the University of the Basque Country (EHU06/
52) and by the Department of Industry, Commerce and
Tourism of the Basque Government (ETORTEK07/25).
G.A. acknowledges the receipt of a PhD grant from the
University of the Basque Country.
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