1
Forecasting water consumption in Spain using univariate time series
models
Jorge Caiadoa
a
Department of Economics and Management, School of Business Administration/Polytechnic Institute
of Setúbal, and CEMAPRE/Technical University of Lisbon, Campus do IPS, Estefanilha, 2914-503
Setúbal, Portugal. Tel.: +351 265 709 438. Fax: +351 265 709 301. E-mail: jcaiado@esce.ips.pt
Abstract: In this paper, we examine the daily water demand forecasting performance of double seasonal
univariate time series models (Exponential Smoothing, ARIMA and GARCH) based on multi-step ahead forecast
mean squared errors. We investigate whether combining forecasts from di¤erent methods and from di¤erent
origins and horizons could improve forecast accuracy. We use daily data for water consumption in Spain from 1
January 2001 to 30 June 2006.
Keywords: ARIMA; Combined forecasts; Double seasonality; Exponential Smoothing; Forecasting; GARCH;
Water demand.
1. Introduction
Water demand forecasting is of great economic
and environmental importance. Many factors
can in‡uence directly or indirectly water consumption. These include rainfall, temperature,
demography, pricing and regulation. Weather
conditions have been widely used as inputs of
multivariate statistical models (regression, transfer function, vector autoregression, and arti…cial neural networks) for water demand modelling and forecasting. See Maidment and Miaou
(1986), Fildes, Randall and Stubbs (1997), Zhou
et al. (2000), Jain, Varshney and Joshi (2001),
Bougadis, Adamowski and Diduch (2005), and
Gato, Jayasuriya and Roberts (2007). These approaches have drawbacks in water demand prediction as a result of weather conditions variability
and changes.
Water demand is highly dominated by daily,
weekly and yearly seasonal cycles. The univariate time series models based on the historical data
series can be quite useful for short-term demand
forecasting as we accommodate the various periodic and seasonal cycles in the model speci…cations and forecasts. To improve forecast accuracy, we may then combine forecasts derived from
the various univariate methods and from di¤er-
ent forecast horizons. Combining forecasts can
reduce errors by averaging of independent forecasts, and is particularly useful when we are uncertain about which forecasting method is better for future prediction. Some relevant empirical
studies using combined forecasts are summarized
in Clemen (1989) and Armstrong (2001).
In this paper, we examine the daily water demand forecasting performance of double seasonal
univariate time series models based on multi-step
ahead forecast mean squared errors. We investigate whether combining forecasts from di¤erent
methods and from di¤erent origins and horizons
could improve forecast accuracy. The most accuracy forecasting methods are then used for outof-sample daily and weekly average forecasting of
water consumption in Spain. Our interest in this
problem arose from time series competition organized by Spanish IEEE Computational Intelligence Society at the SICO’2007 Conference.
The remainder of the paper is organized as follows. Section 2 discusses the methodology used
in time series modelling and forecasting. Section
3 describes the dataset used in the study. Section
4 presents the empirical results. Section 5 o¤ers
some concluding remarks.
2
2. Methodology
2.1. Forecast evaluation
Denote the actual observation for time period t
by Yt and the forecasted value for the same period
by Ft . The mean squared error (MSE) statistic
for the post-sample period t = m+1; m+2; :::; m+
h is de…ned as follows:
M SE =
1
h
m+h
X
1 t=m+1
(Yt
2
Ft ) .
(1)
This statistic is used to evaluate the out-ofsample forecast accuracy using a training sample of observations of size m < n (where n is the
sample size) to estimate the model, and then computing recursively the one-step ahead forecasts for
time periods m + 1, m + 2, ... by increasing the
training sample by one. For k-step ahead forecasts, we begin at the start of the training sample and we compute the forecast errors for time
periods t = m + k, m + k + 1, ... using the same
recursive procedure.
2.2. Random walk
The naïve version of the random walk model is
de…ned as
Ft+1 = Yt .
(2)
This purely deterministic method uses the most
recent observation as a forecast, and is used as
a basis for evaluating of time series models described below.
2.3. Exponential smoothing
Exponential smoothing is a simple but very
useful technique of adaptive time series forecasting. Standard seasonal methods of exponential smoothing includes the Holt-Winters’ addtive
trend, multiplicative trend, damped aditive trend
and damped multiplicative trend (see Gardner,
2006). We implemented the double seasonal versions of the Holt-Winters’ exponential smoothing
(Taylor, 2003) in order to take into account the
two seasonal cycle periods in the water consumption (daily and weekly). The double seasonal additive methods outperformed the double seasonal
multiplicative methods. Within the double seasonal additive methods, the additive trend was
found to be the best for one-step ahead forecasting.
The forecasts for Taylor’s exponential smoothing for double seasonal additive method with additive trend are determined by the following expressions:
Lt = (Yt St 7 Dt 365 )
+ (1
)(Lt 1 + Tt 1 )
Tt = (Lt Lt 1 ) + (1
)Tt 1
St = (Yt Lt Dt 365 ) + (1
)St 7
Dt = (Yt Lt St 7 ) + (1
)Dt 365
(3)
(4)
(5)
(6)
Ft+h = Lt + Tt h + St+h 7 + Dt+h 365 + h
[Yt (Lt 1 Tt 1 St 7 Dt 365 )] (7)
where Lt is the smoothed level of the series; Tt is
the smoothed additive trend; St is the smoothed
seasonal index for weekly period s1 = 7; Dt
is the smoothed seasonal index for daily period
s1 = 365;
and
are the smoothing parameters for the level and trend; and are the seasonal smoothing parameters; is an adjustment
for …rst-order autcorrelation; and Ft+h is the forecast for h periods ahead, with h 7. We initialize
the values for the level, trend and seasonal periods as follows:
365
L365
T365
S1
D1
=
=
1 X
Yt
365 t=1
1
3652
= Y1
= Y1
730
X
t=366
Yt
365
X
t=1
Yt
!
L7 ; :::; S7 = Y7 L7
L365 ; :::; D365 = Y365
L365
The smoothing parameters , , , and
are chosen by minimizing the MSE statistic for
one-step-ahead in-sample forecasting using a linear optimization algorithm.
2.4. ARIMA model
We implemented a double seasonal multiplicative ARIMA model (see Box, Jenkins and Reinsel,
1994) of the form:
3
p (B)
P1 (B
s1
)
P2 (B
s2
)(1
B)d
(1 B s1 )D1 (1 B s2 )D2 (Yt c)
= q (B) Q1 (B s1 ) Q2 (B s2 )"t
(8)
where c is a constant term; B is the lag operator such that B k Yt = Yt k ; p (B) and
q (B) are regular autoregressive and moving average polynomials of orders p and q; P1 (B s1 ),
s2
s1
s2
P2 (B ),
Q1 (B ) and
Q2 (B ) are seasonal
autoregressive and moving average polynomials of orders P1 , P2 , Q1 and Q2 ; s1 and s2
are the seasonal periods; d, D1 and D2 are
the orders of integration; and "t is a white
noise process with zero mean and constant variance. The roots of the polynomials p (B) = 0,
s2
s1
q (B) = 0,
P2 (B ) = 0,
P1 (B ) = 0,
s2
s1
Q2 (B ) = 0 should lie outQ1 (B ) = 0 and
side the unit circle. This model is often denoted
as ARIMA(p,d,q) (P1 ,D1 ,Q1 )s1 (P2 ,D2 ,Q2 )s2 .
We examine the sample autocorrelations and the
partial autocorrelations of the di¤erenced series
in order to identify the integer’s p, q, P1 , Q1 ,
P2 and Q2 . After identifying a tentative ARIMA
model, we estimate the parameters by Marquardt
nonlinear least squares algorithm (for details, see
Davison and MacKinnon, 1993). We check the
adequacy of the model by using suitable …tted
residuals tests. We use the Schwarz Bayesian Criterion (SBC) for model selection.
2.5. GARCH model
In many practical applications to time series
modelling and forecasting, the assumption of nonconstant variance may be not reliable. The models with nonconstant variance are referred to as
conditional heteroscedasticity or volatility models. To deal with the problem of heteroscedasticity in the errors, Engle (1982) and Bollerslev (1986) proposed the autoregressive conditional heteroskedasticity (ARCH) and the generalized ARCH (or GARCH) to model and forecast the conditional variance (or volatility). The
GARCH(p,q) model assumes the form:
2
t
=!+
p
X
j=1
2
j t j
+
q
X
i=1
2
i "t i ,
(9)
where p is the order of the GARCH terms and
q is the order of the ARCH terms. The necessary conditions for the model (9) to be variance and covariance stationary are: ! > 0;
= 1; :::; p; i
0, j = 1; :::; q; and
Pj p 0, j P
q
j=1 j +
i=1 i < 1. Last summation quanti…es the shock persistence to volatility. A higher
persistence indicates that periods of high (slow)
volatility in the process will last longer. In most
economical and …nancial applications, the simple
GARCH(1,1) model has been found to provide a
good representation of a wide variety of volatility processes as discussed in Bollerslev, Chou and
Kroner (1992).
In order to capture seasonal and cyclical components in the volatility dynamics, we implemented a seasonal-periodic GARCH model of the
form:
2
t
= !+
+
2
1 t 1
+
2
365 "t 365
+
2
1 "t 1
M
X
m=1
+
m
2
7 "t 7
cos
2 mSt
7
2 mSt
2 mDt
+'m sin
+ m cos
7
365
2 mSt
2 mDt
+ 0m "2t 7 cos
+ m sin
365
7
2 mDt
2 mSt
+ 0m "2t 365 cos
+'0m "2t 7 sin
7
365
2 mDt
+ 0m "2t 365 sin
,
(10)
365
where St and Dt are repeating step functions with
the days numerated from 1 to 7 within each week,
and from 1 to 365 within each year, respectively.
This approach was used by Campbell and Diebold
(2005) to model conditional variance in daily average temperature data, and by Taylor (2006) to
forecast electricity consumption. We set M = 3
for the Fourier series. We estimate the model by
the method of maximum likelihood, assuming a
generalized error distribution (GED) for the innovations series (see Nelson, 1991).
2.6. Combining forecasts
We examine whether combining forecasts from
the various univariate methods and from di¤erent
4
forecast origins and horizons could provide more
accurate forecasts than the individual methods
being combined. We consider all possible combinations of the forecast methods Holt-Winters
(HW), ARIMA (A) and GARCH (G), and we
compute the simple (unweighted) average of the
forecasts,
= 8 = 0, and 1 = 2 = 0.
3 = 0, 1 =
The estimated results are shown in Table 1. We
…tted a signi…cant parameter ARIMA-GARCH
model of the form:
(1
(1
= (1
Ft =
(HW )
Ft
(A)
Ft
+
+
(G)
Ft
3
,
(11)
where
is the forecasted value of method ( )
in time period t. We drop the random walk (the
worst method) of the combination.
3. Data
We analyze the daily water consumption series in Spain from 1 January 2001 to 30 June
2006 (2006 observations). We have drop February 29 in the leap year 2004 in order to maintain 365 days in each year. This series is plotted
in Figure 1. The dataset was obtained from the
Spanish IEEE Computational Intelligence Society
(http://www.congresocedi.es/2007/).
We use the …rst 1976 observations from 1 January 2001 to 31 May 2006 as training sample for
model estimation, and the remaining 30 observations from 1 June 2006 to 30 June 2006 as postsample for forecast evaluation.
4. Empirical study
4.1. Estimation results
The implementation of the double seasonal
Holt-Winters method to the water demand series Yt gives the values:
= 0:000,
= 0:755,
= 0:303, = 0:294 and = 0:607.
After evaluating di¤erent ARIMA formulations, we apply the following multiplicative double seasonal ARIMA model:
(1
(1
= (1
1B
7
2B
B )(1
9B
9
2
B
)(1
This model
ARIMA(4; 0; 9)
4B
365
4
)(Yt
3B
21
)(1
1B
7
2B
14
)
c)
)(1
can be
(2; 1; 3)7
1B
365
)"t
represented as
(0; 1; 1)365 , with
2B
B )(1
9B
9
2
B
)(1
4B
365
4
)(Yt
3B
)(1
1B
7
2B
14
)
c)
21
)(1
1B
365
)"t
and
2
t
()
Ft
1B
7
= !+
2
1 t 1
+'1 sin
+
2 Dt
365
2
1 "t 1
+
+ '03 "2t
2
365 "t 365
365
sin
6 Dt
365
The model estimates are given in Table 2.
4.2. Forecasting results
The performance of the estimated univariate
methods were evaluated by computing MSE statistics for multi-step forecasts from 1 to 7 days
ahead. Table 3 gives the forecasts results for the
post-sample period from 1 June 2006 to 30 June
2006. Table 4 gives the forecast results for the
weekly 7-days of the same post-sample period.
The ARIMA and GARCH models appear to
have the same forecast performance for all the
forecast horizons. The Holt-Winters outperformed the ARIMA and GARCH models in long
horizons. In contrast, for one to four steps ahead
forecasting the ARIMA and GARCH models performed better than the Holt-Winters. The random walk model ranked last for any of the forecast horizons considered.
For the 7-days of week, the ARIMA appear
to perform well for Monday and Tuesday forecasting, the simple combinations Holt-ARIMA
and Holt-GARCH appear to be most useful for
Wednesday forecasting, the Holt appears to be
the most appropriate method for Thursday, Friday and Sunday forecasting, and the GARCH appears to be the best method for Sunday forecasting.
In Table 5 we present the out-of-sample forecasts for water demand series. Our forecasts are
based on the most accuracy forecasting method
used for multi-step ahead average forecasting for
the 7-days cycle. We consider the periods from
1 July to 31 July 2006 (31 daily forecasts), from
.
5
14
12
10
8
6
4
2
0
Jan-01
Jan-02
Jan-03
Jan-04
Jan-05
Figure 1. Daily water demand in Spain for the period 1 January 2001 to 30 June 2006
Jan-06
6
1 July to 29 December 2006 (26 weekly average
forecasts) and from 3 July to 31 December 2006
(26 weekly average forecasts).
5. Concluding remarks
In this paper, we compared the forecast accuracy of individual and combined univariate
time series models for multi-step-ahead water demand forecasting. We implemented double seasonal versions of the Holt-Winters, ARIMA and
GARCH models in order to accommodate the
two seasonal cycles periods in water consumption
(daily and weekly).
The empirical results suggest that all the univariate time series models can be quite useful for
short-term forecasting. Moreover, the examination of the multi-step-ahead forecasting performance for each day of week suggest the use of different methods and di¤erent combined forecasts
to improve forecasting accuracy.
REFERENCES
1. Armstrong, J. (2001). "Combining forecasts",
in Principles of Forecasting: A Handbook for
Researchers and Practitioners, J. S. Armstrong (ed.), Kluwer Academic Publishers.
2. Bollerslev, T. (1986). "Generalized autoregressive conditional heteroskedasticity",
Journal of Econometrics, 31, 307-327.
3. Bollerslev, T., Chou, R. and Kroner, K.
(1992). "ARCH modeling in Finance", Journal of Econometrics, 52, 5-59.
4. Bougadis, J., Adamowski, K. and Diduch,
R. (2005). "Short-term municipal water deamand forecasting", Hydrological Processes,
19, 137-148.
5. Box, G., Jenkins, G. and Reinsel, G. (1994).
Time Series Analysis: Forecasting and Control, 3rd ed., Prentice-Hall, New Jersey.
6. Campbell, S. and Diebold, F. (2005).
"Weather forecasting for weather derivatives", Journal of the American Statistical
Association, 100, 6-16.
7. Clemen, R. (1989). "Combining forecasts: a
review and annoted bibliography", International Journal of Forecasting, 5, 559-584.
8. Davison, R. and MacKinnon, J. (1993). Estimation and Inference in Econometrics, Oxford University Press, Oxford.
9. Engle, R. (1982). "Autoregressive conditional
heteroscedasticity with estimates of the variance of United Kingdom in‡ation", Econometrica, 50, 987-1008.
10. Fildes, R., Randall, A. and Stubbs, P. (1997).
"One-day ahead demand forecasting in the
utility industries: Two case studies", Journal of the Operational Research Society, 48,
15-24.
11. Gardner Jr., E. (2006). "Exponential smoothing: The state of the art - Part II", International Journal of Forecasting, 22, 637-666.
12. Gato, S., Jayasuriya, N. and Roberts, P.
(2007). "Temperature and rainfall thresholds
for base use urban water demand modelling",
Journal of Hydrology, 337, 364-376.
13. Jain, A., Varshney, A. and Joshi, U. (2001).
"Short-term water demand forecast modeling at IIT Kanpur using arti…cial neural networks", Water Resources Management, 15,
299-231.
14. Maidment, D. and Miaou, S. (1986). "Daily
water use in nine cities", Water Resources Research, 22, 845-851.
15. Nelson, D. (1991). "Conditional heteroskedasticity in asset returns: a new approach",
Econometrica, 59, 347-370.
16. Taylor, J. (2003). "Short-term electricity demand forecasting using double seasonal exponential smoothing", Journal of the Operational Research Society, 54, 799-805.
17. Taylor, J. (2006). "Density forecasting for the
e¢cient balancing of the generation and consumption of electricity", International Journal of Forecasting, 22, 707-724.
18. Zhou, S., McMahon, T., Walton, A. and
Lewis, J. (2000). "Forecasting daily urban
water demand: a case study of Melbourne",
Journal of Hidrology, 236, 153-164.
7
Table 1
Seasonal ARIMA model estimates for water demand series
Model: ARIMA(4,0,9) (2,1,3)7 (0,1,1)365
Parameter Lag Estimate Standard error
c
-0.004
0.007
1
0.592
0.025
1
2
0.134
0.027
2
4
0.061
0.023
4
9
0.053
0.024
9
7
-0.757
0.023
1
14
-0.561
0.029
2
21
-0.366
0.032
3
365
-0.644
0.023
1
Residual ACF
Lag Estimate
1
0.004
2
0.009
3
-0.020
4
0.001
5
-0.026
6
0.015
7
-0.010
Residual PACF
Lag Estimate
1
0.004
2
0.009
3
-0.020
4
0.001
5
-0.025
6
0.015
7
-0.010
R2 adjusted = 0.662
Q(20) = 18:31 (0.11)
Q2 (20) = 71:62 (0.00)
Notes: Q(20) (Q2 (20)) is the Ljung-Box statistic for serial correlation in the residuals (squared residuals) up to
order 20; p-value in parentheses.
Table 2
Seasonal-periodic GARCH model estimates for water demand series
Model: ARIMA(4,0,9) (2,1,3)7 (0,1,1)365 -GARCH(1,1) (0,1)365
Residual ACF
Parameter
Lag
c
1
2
4
9
1
2
3
1
1
2
4
9
7
14
21
365
!
1
1
365
'1
'03
GED
1
1
365
365
Estimate
-0.011
0.502
0.137
0.075
-0.064
-0.747
-0.534
-0.346
-0.640
0.107
0.103
0.483
0.109
0.026
0.062
1.361
Standard error
0.008
0.029
0.030
0.024
0.023
0.023
0.028
0.031
0.025
0.028
0.037
0.108
0.032
0.011
0.035
0.055
Lag
1
2
3
4
5
6
7
Estimate
-0.007
0.023
-0.028
-0.026
-0.042
0.026
-0.006
Squared residual ACF
Lag
Estimate
1
0.012
2
-0.030
3
0.028
4
0.018
5
0.008
6
-0.023
7
0.015
Lag
1
2
3
4
5
6
7
Residual PACF
Estimate
0.007
0.023
-0.028
-0.026
-0.040
0.027
-0.006
Squared residual PACF
Lag
Estimate
1
0.012
2
-0.031
3
0.029
4
0.016
5
0.009
6
-0.023
7
0.015
R2 adjusted = 0.657
Q(20)=19.20 (0.08)
Q2 (20)=13.61 (0.33)
Notes: As Table 1.
8
Table 3
MSE for multi-step-ahead forecasts for post-sample period
Forecast
horizon
1-step
2-step
3-step
4-step
5-step
6-step
7-step
Average
RW
0.96
1.55
1.82
2.09
2.23
1.91
1.33
1.70
HW
0.38
0.51
0.49
0.48
0.43
0.42
0.40
0.44
ARIMA
0.35
0.45
0.47
0.45
0.44
0.45
0.44
0.44
GARCH
0.35
0.45
0.45
0.46
0.46
0.47
0.46
0.44
HW-A
0.35
0.46
0.45
0.46
0.43
0.43
0.41
0.43
Combined
HW-G
0.35
0.45
0.45
0.46
0.43
0.43
0.42
0.43
forecasts
A-G HW-A-G
0.35
0.35
0.45
0.45
0.45
0.45
0.46
0.46
0.45
0.44
0.46
0.44
0.45
0.43
0.44
0.43
Table 4
MSE for multi-step ahead forecasts for weekly 7-days in post-sample period
Forecast
horizon
1-step
Days of
week
Monday
Tuesday
Wednesday
Thursday
Friday
Saturday
Sunday
RW
16.18
0.28
0.18
3.15
0.47
3.00
1.20
HW
2.33
0.53
0.14
4.19
0.37
0.23
1.26
ARIMA
1.18
0.20
0.25
5.26
0.54
0.64
0.40
GARCH
1.25
0.19
0.26
5.40
0.54
0.58
0.33
HW-A
1.71
0.34
0.19
4.71
0.45
0.39
0.70
Combined
HW-G
1.75
0.34
0.20
4.78
0.45
0.37
0.61
forecasts
A-G HW-A-G
1.21
1.55
0.19
0.29
0.26
0.21
5.33
4.93
0.54
0.48
0.61
0.45
0.36
0.53
4-step
Monday
Tuesday
Wednesday
Thursday
Friday
Saturday
Sunday
3.86
2.66
8.39
11.27
1.83
4.14
10.23
0.42
0.15
0.48
3.63
1.78
1.29
3.23
0.43
0.16
0.69
3.79
1.88
1.21
1.10
0.54
0.17
0.77
4.14
1.94
1.26
0.81
0.42
0.15
0.58
3.71
1.83
1.25
2.03
0.48
0.15
0.62
3.88
1.86
1.28
1.82
0.48
0.16
0.73
3.96
1.91
1.24
0.95
0.46
0.16
0.64
3.85
1.87
1.25
1.56
7-step
Monday
Tuesday
Wednesday
Thursday
Friday
Saturday
Sunday
0.30
0.15
1.09
13.60
7.91
4.19
0.70
0.19
0.07
0.27
2.54
2.14
1.43
1.14
0.24
0.06
0.39
3.33
2.25
1.48
0.29
0.38
0.08
0.29
3.42
2.38
1.59
0.22
0.21
0.06
0.33
2.92
2.19
1.46
0.63
0.28
0.06
0.28
2.96
2.26
1.51
0.51
0.30
0.06
0.34
3.38
2.32
1.54
0.26
0.26
0.06
0.31
3.08
2.26
1.50
0.42
Average
Monday
Tuesday
Wednesday
Thursday
Friday
Saturday
Sunday
4.79
4.13
4.89
7.52
5.21
4.02
6.10
0.61
0.44
0.43
3.01
1.99
1.06
2.35
0.55
0.16
0.46
3.71
2.25
1.24
0.68
0.65
0.17
0.48
3.91
2.32
1.26
0.50
0.57
0.25
0.41
3.33
2.12
1.13
1.38
0.62
0.26
0.41
3.43
2.15
1.14
1.22
0.59
0.16
0.47
3.80
2.28
1.25
0.59
0.59
0.21
0.42
3.51
2.18
1.17
1.02
9
Table 5
Out-of-sample daily and weekly average forecasts for water demand series
Forecast
period
1 July 2006
2 July 2006
3 July 2006
4 July 2006
5 July 2006
6 July 2006
7 July 2006
8 July 2006
9 July 2006
10 July 2006
11 July 2006
12 July 2006
13 July 2006
14 July 2006
15 July 2006
16 July 2006
17 July 2006
18 July 2006
19 July 2006
20 July 2006
21 July 2006
22 July 2006
23 July 2006
24 July 2006
25 July 2006
26 July 2006
27 July 2006
28 July 2006
29 July 2006
30 July 2006
31 July 2006
Daily
forecasts
9.3393
9.4614
8.6222
10.3095
9.9691
9.6744
9.4109
8.0849
8.4503
7.6937
9.5814
9.3338
9.2385
9.1268
7.7251
8.3192
7.7194
9.2434
9.1702
9.1609
8.6665
7.4185
8.2409
7.7286
9.2441
9.0913
8.9348
8.6137
7.2653
8.0448
7.5470
Forecast
period
1 Jul -7 Jul
8 Jul-14 Jul
15 Jul -21 Jul
22 Jul -28 Jul
29 Jul - 4 Aug
5 Aug - 11 Aug
12 Aug - 18 Aug
19 Aug - 25 Aug
26 Aug - 1 Sep
2 Sep - 8 Sep
9 Sep - 15 Sep
16 Sep - 22 Sep
23 Sep - 29 Sep
30 Sep - 6 Oct
7 Oct - 13 Oct
14 Oct - 20 Oct
21 Oct - 27 Oct
28 Oct - 3 Nov
4 Nov - 10 Nov
11 Nov - 17 Nov
18 Nov - 24 Nov
25 Nov - 1 Dec
2 Dec - 8 Dec
9 Dec- 15 Dec
16 Dec - 22 Dec
23 Dec - 29 Dec
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
Average
forecasts
9.5410
8.7871
8.5721
8.4674
8.1969
7.8059
7.3662
7.6512
8.0755
8.3625
8.4238
8.4734
8.3959
8.3155
7.8275
7.5310
7.6197
7.5537
7.9359
7.9195
7.7142
7.6954
7.2456
7.6863
7.5248
7.0362
Forecast
period
3 Jul -9 Jul
10 Jul-16 Jul
17 Jul -23 Jul
24 Jul -30 Jul
31 Jul - 6 Aug
7 Aug - 13 Aug
14 Aug - 20 Aug
21 Aug - 27 Aug
28 Aug - 3 Sep
4 Sep - 10 Sep
11 Sep - 17 Sep
18 Sep - 24 Sep
25 Sep - 1 Oct
2 Oct - 8 Oct
11 Oct - 15 Oct
16 Oct - 22 Oct
21 Oct - 29 Oct
30 Oct - 5 Nov
6 Nov - 12 Nov
13 Nov - 19 Nov
20 Nov - 26 Nov
27 Nov - 3 Dec
4 Dec - 10 Dec
11 Dec- 17 Dec
18 Dec - 24 Dec
25 Dec - 31 Dec
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
2006
Average
forecasts
9.2173
8.7170
8.5171
8.4175
8.0443
7.7455
7.3417
7.7199
8.2972
8.2373
8.4191
8.5735
8.3159
8.3421
7.5624
7.5278
7.6764
7.6166
7.9908
7.8022
7.8061
7.5147
7.3100
7.7958
7.3708
6.9743