Green: Text revised.
Red: Text added
Policy Implications of the Lucas Critique Empirically Tested along Global Financial Crisis
Amira Karimova , Esra Simsek and Mehmet Orhan
This study is the first attempt to facilitate the substantial change in post-crisis monetary policy of the Fed to test the validity of Lucas Critique (LC) towards exploring implications of such changes for policymaking. Global financial crisis (GFC), asking for fundamental regime alterations presented an invaluable opportunity to test the empirical validity of LC. We make use of quarterly US data over 1990-2015 to test for superexogeneity, the rejection of which lends support to LC. We define the marginal models for wealth, GDP and Treasury Bill rate to construct the conditional model of money demand following Hendry (1988). Our results reject superexogeneity of the policies and report the support for LC. We discuss about the details and consequences of the monetary policy followed to suggest arguments to prolonging debates on policy discussions.
Keywords: Lucas Critique, Monetary Policy, Superexogeneity, Invariance, Rational Expectations, Microfoundations.
JEL Classification Codes: C22; C52; E41; E42; E52; E58.
Introduction and Research Background
1.a. Lucas Critique
Lucas Critique, with its empirical validity still under debate more than four decades after its inception, has serious policy implications. Economic agents, firms and institutions in any country under the administration of financial and fiscal authorities are directly influenced from policy objectives and regime changes. The impact of policy changes on nominal and real macroeconomic indicators is critical and crucial. Yet, there is still harsh debate on the consequences of monetary and fiscal regime changes. In this regards, critique posed by 1995 Nobel Laureate Robert E. Lucas is a milestone to assess the results of policy changes and presents beneficial and effective clues about policy design.
Lucas argues that macroeconometric models that do not handle optimizing behavior of rational agents at policy changes are subject to failure. Assuming that the agents are forward looking, their economic decisions will depend partly on future actions of the policymakers. Lucas suggests that the linkage between the regime changes by policymakers in the future and forecasts of agents handling these changes should be included in econometric models. Lucas’s contribution to policy evaluation was revolutionary since he has demonstrated that conventional backward-looking models ignored the formation of expectations which is the key determinant of agent’s behavior in case of a policy regime change. LC depends on the formation of expectations substantially. By his critique, Lucas made it clear that policies cannot be evaluated within the classical theory, and conventional macroeconometric models cannot be used to investigate policy changes since the structural parameters do change as policy does.
The critique can be summarized by the most quoted expression of it as “Given that the structure of an econometric model consists of optimal decision rules of economic agents, and that optimal decision rules vary systematically with changes in the structure of series relevant to the decision maker, it follows that any change in policy will systematically alter the structure of econometric models.” Implicitly stated in this expression is that the agents’ optimization problems comprise of parameters used in policy rules. To be more specific, following the notation in Ericsson and Irons (1995), assume that the economy is characterized by the decision rule optimized by the agents, F(.), and the policy reaction function, G(.):
where y_t is the endogenous variable, x_t is the exogenous variable, ?_t and ?_t are shocks at time t, and ? and ? are the parameters of the corresponding functions. The agent optimizes F and has to take care of parameters in G since ? may depend on ? and thus when ? changes due to a regime shift, ? changes directly. The critique posed by Lucas is on theoretical ground and is in deep need of empirical support.
Lucas in his original 1976 paper exemplifies this process with Friedman’s consumption function, taxation, investment demand, and Phillips curve. Lucas had criticized the facilitation of models to estimate the impact of alternative policies arguing that the parameters included in the models are not invariant to shifts in policy. In case of a change in policy, the rational agents modify their expectations and new decision rules are fixed. That is why models based on the decision rules vary due to policy shifts and models without this feature are inferior. The response of macroeconomists to Lucas Critique was the introduction of Dynamic Stochastic General Equilibrium (DSGE) Models where parameters corresponding to preferences and technology are preserved unchanged even if there is a shift of the policy regime with the inevitable assumption of correct DSGE model specification. In a typical DSGE model, variables representing technology and preferences do not vary and are not subject to changes in policy regimes. Once the structural model is correctly specified, estimation of parameters belonging to these variables will not be biased. This very feature of the DSGE models make them free from LC.
1.b. Rational Expectations
The expectations of the agents are at the heart of the critique. LC focuses on how parameters of the econometric models enter the optimization functions of the economic agents. That is, the parameters that policymakers set by changing the policy regimes have to enter the optimization problems of the agents. As policy regimes change, the nature and thus the preferences of the agents do not change but their expectations do. The expectations are addressed to be forward instead of backward-looking after the popularization of the rational expectations revolution in macroeconomics which build on the earlier paper of Muth (1961) that made use of the adaptive expectations by Friedman (1956) and Cagan (1956). The implications of rational expectations on policy analysis are essential, fundamental and remarkable. The main findings of the impact of rational expectations hypothesis on policy regime changes are by Barro (1976), Kydland & Prescott (1977), Lucas (1976), Sargent, Fand, & Goldfeld (1973), Sargent & Wallece (1975).
The rational expectations hypothesis assume that the individuals know the structure of the economy and past values of all variables therein. In addition, the agents are assumed not to make systematic errors since the information set available includes past errors. Shiller (1978), Fischer (1980), Begg (1982), and Sheffrin (1996) are the initial references to rational expectations while earlier studies of rational expectations hypothesis on monetary policy include Sargent (1977), Sargent et al., (1973), Lucas & Sargent (1981), and Lucas & Prescott (1971). The main theme of the debate was policy ineffectiveness that necessitates no effect of anticipated systematic monetary policy on mean and variance of output. That is, systematic monetary policy changes cannot have real effects on the economy. The early versions by Friedman (1968) stated that output was independent of monetary policy in the long run. The paper by Sargent & Wallece (1975) concluded the same for short run. The assumption of agent’s optimization based on rational expectations is so strong to eliminate systematic forecast errors associated with adaptive, regressive, extrapolative or other types of expectations.
Although rational expectations hypothesis deserves its reputation since it addresses the solution to a set of debates, it has introduced its own problems and shortcomings. The main criticism is the so-called construction of the true structure of the economy by individuals who do not know enough about the economy and modeling mathematics while wise economists debate on main and simple issues. Besides, “How do the agents rationalize expectations and learn from the mistakes to get rid of systematic forecast errors?” is another key question to be answered satisfactorily.
A remarkable fundamental problem with the LC is time-inconsistency stressed by the seminal work of Kydland ; Prescott (1977). The optimal policies with forward-looking expectations may become sub-optimal through time, known as time-inconsistency or dynamic inconsistency. That is, ex ante optimal policies may become sub-optimal ex post. LC itself was criticized by many others, as Hendry (2002) indicated “…the critique has been criticized in turn by many authors, including Gordon (1976), Sims (1986), Sims, Goldfeld, & Sachs (1982) and Hendry (1988), and most recently by Salmon & Marcellino (2001), who show the internally-inconsistent use of ‘rationality’ in Lucas’s analysis. There is also scant evidence of its operation empirically (see, in particular, Ericsson & Irons (1995))” In addition, there have been many other such criticisms after early 2000s. See Smith, (2009) for a list of arguments against LC. Although the LC is generally accepted and integrated to mainstream macroeconomic theory, it did not pass rigorous empirical test to assert its validity.
On the other hand, Mishkin (1995) indicates that the LC was revolutionary and underlines the role of expectations as: “Policymakers now recognize the importance of expectations to the outcome of particular policies because of the rational expectations revolution: before the advent of rational expectations, expectations were typically ignored by policymakers when conducting policy analysis” But, there is lack of guidance to policymakers as indicated by Sims (2007) as “…I also criticized the academic econometric and macroeconomic literature, which took no interest in policy modeling and had little guidance to offer policy modelers.”
1.b. Global Financial Crisis and Regime Change in Monetary Policy:
There are several challenges against testing the LC empirically one of which is addressing a fundamental change in policy regime that is fortunately provided to us by the GFC, although we are extremely upset to experience the consequences of it. The 2008 financial crisis had enormous effects on the global economy and posed objections to traditional policy making. The so-called credit tsunami (by Alan Greenspan) of the century, incepted by the mortgage markets, started hitting the financial markets and thus, institutions in June 2007. As a result of the initial devastating strikes of the huge waves, one of the largest US firms that had been a main pillar of the financial system since 1850, Lehman Brothers, filed for bankruptcy, as well as the American International Group (AIG), a giant insurance conglomerate. These two in addition to many similar others, triggered the fears that many institutions would be suffering from substantial losses due to unpaid borrowings that would threaten their solvency. The panic spread to real markets very shortly. These were reflected to the statistics; in the US, the 18-month recession between 2007 and 2009 was the longest recorded post WWII. It led to 6.3 % decline in employment and 5.1% fall in output. Stock prices fell by 50% from October 2007 to March 2009 (“Recession in Perspective”/Federal Reserve Bank of Minneapolis). Tsunami reaching the other parts of the globe through financial and trade channels soon, decreased the Baltic Dry Index, underlining shipping volume and thus international trade, by 50% in October 2008. Japan and Korea, for instance, had 31% and 26% declines in their industrial output from January 2008 to January 2009 (Alzaabi, 2013). The global financial crisis in its “Great Recession” stage marked the worst economic contraction since WWII (Verick ; Iyanatul Islam, 2010). Mishkin (2009) indicated that this was the worst financial crisis that the United States has experienced since the Great Depression. Facing the worst financial crisis ever since the Great Depression the Federal Reserve had aggressively lowered the federal funds rate target from 5.25% in September 2007 to 0 to 0.25% in December 2008 (Mishkin, 2009). As an attempt to alleviate the destructive consequences of the crisis, when Obama’s term at the White House started in 2009, he signed the fiscal stimulus package to increase federal government spending by about $499 billion and reduce taxes by around $288 billion. But managing the detrimental influence of the crisis was extremely complex and beyond such voluminous fiscal policy tools.
The former president of the ECB, Jean-Claude Trichet indicated that the defining characteristic of the global financial crisis had been so perplexing to ask for non-standard monetary policy measures. Although the financial markets of the globe were somehow ubiquitous, the approaches by the central banks were different designed for peculiar economies and their structures ranging from enhanced credit support and credit easing to quantitative easing and interventions in foreign exchange and securities markets. Fahr, Motto, Rostagno, Smets, & Tristani (2011) state “The initial turmoil and the subsequent crisis that swept through financial markets over the past three years have posed unprecedented challenges for central banks. Their policy responses have been equally unprecedented and have involved non-standard measures, i.e. actions that go beyond the usual changes in a “policy” interest rate.” They reason the use of unprecedented non-standard monetary policy as the central banks responsibility to prevent liquidity problems turning into solvency problems with an eventual breakdown of the monetary transmission mechanism. In addition, malfunctioning interbank and other financial markets called upon central banks to take on a more active financial intermediation role.
There was urgent need for accommodative policies of the monetary authorities. As Mishkin (2011b) mentioned, the contractionary shock from the financial crisis was so severe that it overwhelmed the ability of conventional monetary policy to counteract it. One of the remarkable changes in validating unconventional monetary policy has been the Quantitative Easing (QE) program administered by the US after the crisis, and followed by several other central banks. There is a mounting body of recent research on QE and its effects (El-Shagi & Giesen, 2013; Karagiannis, Panagopoulos, & Vlamis, 2010; Mishkin, 2011b; Rogoff, 2017; Taylor, 2014) and almost all of them agree on the fact that QE was, although risky and not desirable, best possible option to respond to the ongoing and future contractionary shocks to the economy. In the process of implementing QE policies, the FED’s balance sheet dramatically expanded from around $700 billion in 2008 to $2.1 trillion in June 2010, with most of the increases absorbed by the banking system as excess reserves (Bernanke, 2012).
QE being applied practically at the same time commenced re-consideration of traditional monetary policy-making which may lead to shed light on the perplexing debate of the LC. Lucas (1976) argues that policy shifts and/or structural changes of the expectation-generating mechanism lead to unstable econometric models, since such changes will alter actual structural parameters and the estimated coefficients in the model. The QE as an agreed upon policy alteration results in the expectation modification of economic agents as well as institutions. In order to be an effective policy tool, parameters of the econometric model must be invariant to these changes. The role of the LC has become very important in evaluating and analyzing the implications of the policies undertaken after the crisis because it may have a powerful influence in decreasing the application of the standard monetary models for the policy analysis. Applicability of the LC, also known as the validity of “deep structural parameters” (Fair, 1987) is significant to accurately assess the future effects of the consequent policy shifts on economic activity and agents’ expectations that are assumed to be “rational”.
1.c. Main Motivation
The empirical testing of the LC is never found satisfactory. As Malinvaud (1997) underlined “Indeed the small illustrative models presented by Lucas and others, showed no more than a possibility and were in no way tested as to their empirical validity.” He continued his criticism stating that “…neither Lucas nor the New Classical macroeconomists had tried to test the empirical validity of the Critique: At the time, many macroeconomists, especially me, were not convinced of the scope of the Lucas Critique, although they recognized the correctness of the remark that inspired it.”
Lucas & Sargent (1981), in their famous After Keynesian Macroeconomics, indicate “Yet the question of whether a particular model is structural is an empirical, not a theoretical one.” Later on, when introducing his collected works in Studies in Business Cycle Theory, Lucas & Sargent (1981) argues again: “…this presumption about policy-invariance seems a sound one to me, but it must be defended on empirical, not logical grounds, and the nature of such a defense presumably would vary with the particular application one has in mind.”
Despite a large amount of research on the LC, there is a surprising lack of empirical study on the issue of testing the empirical validity of critique in the literature . The reasons are various, such as the scarcity of observational period attributed to fundamental change in policy, small samples, and essentially, on top of which is the absence of generally accepted methodology. Unfortunately, neither Lucas nor his immediate companions as well as his followers did not introduce the methodology to test the empirical relevance of the theory. In later years, Engle & Hendry (1993) introduced the concept of superexogeneity, which has appeared to be an effective tool to test the empirical relevance of the Lucas Critique. Subsequent papers (Ericsson & Irons, 1995; Lindé, 2001) have demonstrated how this concept can be applied to check for policy invariance in econometric models. In this way, superexogeneity has been largely performed to test the effects of regime shifts in monetary, exchange rate, consumption and savings rate behavior (Karunaratne, 1996). The works by Boug (1999), Favero & Hendry (1992), Ericsson & Irons (1995), and Lubik & Surico (2010) highlight the importance of the use of the superexogeneity test and consider it as the main empirical tool to assess LC validity after the policy shifts.
There are favorable reasons behind using superexogeneity to test for the validity of LC. As Engle & Hendry (1993) underline, some problematic issues arise when the traditional tests in the literature are used in order to find the relevance of the parameter stability with lack of guidance on exact dates and numbers of breaks. The entire test is misguiding when incorrect days are selected for testing the existence of the structural break (Engle & Hendry, 1993). In such cases, testing for exogeneity with its three different versions is preferable. In the literature three versions of exogeneity are defined: Weak exogeneity is employed for estimation purposes, strong exogeneity is required for forecasting, and superexogeneity (Superexogeneity) is facilitated for policy analysis. Although the superexogeneity test has been used to check for the effects of regime shifts in monetary, exchange rate, consumption and trade policies, there is no attempt on its application with QE in the literature
In the context of these important policy questions, the present period offers an invaluable opportunity to test the validity of LC empirically towards suggestions on policy design. This study applies superexogeneity test (Engle & Hendry, 1993) to detect the relevance of the LC in modelling the demand for money in the U.S. after the three QE attempts. The related literature recommends that the LC should be assessed in the context of economic models that would deal explicitly with expectations, such as the money demand function used in this paper (Hurn & Muscatelli, 1992; Engle & Hendry, 1993). We also provide policy discussions that shed light on the fragility of conventional models to capture existing information and provide correct policy implications in the environment of major shifts such as QE. As per the conclusion of the empirical testing of superexogeneity, rejection over the sample period indicates that the parameters are variant/sensitive to the policy changes and implies that the LC is relevant.
Empirical studies making use of superexogeneity in the literature are scarce and studies based on superexogeneity methodology to test the LC in monetary models, and almost all existing papers are outdated. One of the rare studies is by Hurn & Muscatelli (1992) who found that the LC may not be relevant in the case of the demand for money (M4) in the UK. Others such as Karunaratne (1996), Valadkhani (1998), Caporale (1996), Faria & León-Ledesma (2005), Belke (2000), Oliveira & Santos (2007), Psaradakis & Sola (1996), Santos (2004), and Liu & Morley (2014) investigated the same issue but with applications to trade, consumption, business cycle and financial models using data chronologically back to older decades. Following the findings in superexogeneity methodology from earlier studies, this paper is organized as follows: Section 2 briefly describes the procedures for testing invariance and superexogeneity hypotheses. Section 3 outlines and estimates a model of the demand for money in the U.S. The following section 4 provides discussions of the estimated results with policy implications and finally section 5 concludes.
There have been numerous attempts to test the constancy of parameters over the historical period. One of the initial specification tests is by Chow (1960), which simply questions for interactions with dummy variables (Engle & Hendry, 1993). In contrast, superexogeneity is specifically designed to ascertain whether parameters are likely to remain constant in response to changes in policy regime over the historical period. As an important measure of parameter stability, it is closely related to the test of invariance, but the causes, periods and magnitudes of changes are identified by the economic circumstances, and the historical evidence for regime changes are embodied in the conditioning variables. The superexogeneity test is perfectly applicable to the models of money demand, and the Phillips curve, in particular. Indeed, the instability of the Phillips curve, especially at times of external shocks and regime changes, was probably the most famous application of the influential “Lucas Critique” (Bajo-Rubio, Díaz-Roldán, & Esteve, 2007). Due to the lack of opportunities of major monetary policy shifts until the global crisis, the superexogeneity tests were used in applications with exchange rate, consumption, and savings models that entail relatively minor policy shifts in the literature. The studies include Ericsson (1992), Favero & Hendry (1992), Caporale (1996), Karunaratne (1996), Valadkhani (1998), and Habibullah, Azali, & Baharumshah (2001) who examine the relevance of the Lucas Critique.
Many econometric studies require the distinction between exogenous and endogenous variables to build the model for statistical inference. In this regards, exogeneity is the key to many econometric analyses, but there are difficulties concerning the very definition of the term (Engle, Hendry, & Richard, 1983). This inconvenience asks for further investigation of estimation on model parameters. Fortunately, Engle et al., (1983) contribute to the literature arguing that the superexogeneity is closely related to the Lucas Critique and, as mentioned in Caporale (1996), serves as an important instrument for policy analysis.
We provide the brief explanation of the superexogeneity testing procedure employed to assess the relevance of the LC below. A more detailed and complete procedure of the testing strategy for superexogeneity is provided by Engle et al. (1983). We start by defining the joint, conditional and marginal distributions following Engle et al. (1983) as:
F_k (k_t;?_t )=F_(y|x) (y_t?x_t;?_1t ).F_x (x_t;?_2t)
where F_(y|x) and F_x are conditional and marginal models.
As per two of the three versions of exogeneity mentioned; a variable x_t is said to be weakly exogenous for a set of parameters of interest ? (some functions of ?) in a conditional model of a variable y_t with parameters ?_1 with ?k_t=(y_t ?,x?_t )?^’ if:
? is a function of the parameters ?_1t alone;
?_1t and the parameters of the marginal model for x_t, and ?_2t are variation free, which implies that there is no loss of information about ? from neglecting the marginal model (Caporale, 1996).
x_t is defined as super exogenous for ? if:
x_t is weakly exogenous for ?,
changes in ?_2t do not cause changes in ?_1t. Here, a parameter is considered invariant for a class of interventions if it remains constant under these interventions. A model is invariant for such interventions if all its parameters are (Engle et al., 1983)
Illustratively, Engle et al. (1983) model the linear regression equation, which is hypothesized to represent the constant conditional mean of a random variable y_t given another random variable x_t as well as other information. These technical definitions are key to suggesting principles for designing policies since distinction between exogenous and endogenous variables enables us to figure out variables invariant to policy changes. Consider the joint distribution of these variables conditional normal with the following conditional means:
Ey_t?I_t =?_t^y (1)
and covariance matrix
?_t=?(?^yy;?^[email protected]?^xy;?^xx ) (2)
where x_t and y_t are conditional on the information set I_t that contains their past values, and current and past values of other valid conditioning variables z_t. The conditional expectation of y_t on x_t can be expressed as:
E(y_t?x_t )=?_t (x_t-?_t^x )+?_t^y (3)
y_t-E(y_t?x_t )=?_t (4)
where ?_t is the regression coefficient of y_t on x_t equals to ?^yx/?^xx, and ?_t is the conditional variance equals to ?^yy-(?^yx )^2/?_t^xx.
The conditional mean of y_t and x_t is considered in the following behavioral relationship as:
?_t^y=??_t^x+z_t^’ ? (5)
Combining Equations 3, 4 and 5 yields:
y_t=?x_t+z_t^’ ?+(?_t-?)( x_t-?_t^x )+?_t (6)
To sustain this regression analysis with weakly exogenous, constant and invariant parameters we need the following three conditions:
Weak exogeneity of x_t for the parameters of interest. This requires that ?_t^x, ?_t^xx, and ?_t^yx do not enter the conditional model, which is satisfied if ?_t=?.
Constancy of the parameters that requires ?_t=?. Since ?_t=?^yx/?^xx, the regression model is homoscedastic if ?^yy=?+??_t^xx.
Invariance of ? to the changes in the processes generating z_t.
With these conditions satisfied, a standard regression model to be estimated is:
y_t=?x_t+z_t^’ ?+?_t (7)
Towards testing for the empirical validity of the LC, Engle & Hendry (1993) show that the effects of policy shifts can be formulated as the impact of changes in the moments of x_t on the parameters of ? in the following linear expansion form:
?=?_0+?_1 ?_t^x+?_2 ?_t^xx+?_3 ?(??_t^xx/?_t^x) (8)
By substituting (8) into (7) we obtain:
?_t^y=?_0+?_1 ?_t^x+?_2 ?_t^xx+?_3 ?(??_t^xx/?_t^x) ?_t^x+z_t^’ ? (9)
or in the following form as a regression:
y_t=?_0 x_t+z_t^’ ?+(?_t-?_0 )( x_t-?_t^x )+?_1 ?(?_t^x)?^2+?_2 ?_t^x ?_t^xx+?_3 ?_t^xx+?_1t (10)
For superexogeneity, the moments of x_t should be insignificant and ?_t must be constant over time. However, when ?_t is not constant, Engle & Hendry (1993) suggest a linear expansion, such as:
?_t=?^yx/?^xx=?_0+?_1 ?^xx (11)
By combining Equations (6), (8), and (11) we obtain a general alternative regression for the case of non-constant ?_t:
y_t=?_0 x_t+z_t^’ ?+(?_0-?_0 )( x_t-?_t^x )+?_1 ( x_t-?_t^x ) ?^xx+?_1 ?(?_t^x)?^2+?_2 ?_t^x ?_t^xx+?_3 ?_t^xx+?_2t (12)
Equations (10) and (12) can be implemented to test for superexogeneity by examining both a conditional model and marginal models for the conditioning variables. Here, we can interpret conditional and marginal models as agents’ and policy makers’ decision rules, respectively (Giersbergen ; Kiviet, 1996). Since policy makers often set targets for the endogenous variables that determine the behavior of the economic agents, policy rules are affected from past economic outcomes. (Banerjee, Hendry, ; Mizon, 1996). Economically, superexogeneity occurs when the agents form their expectations without using models, for instance the high cost of information or a low level of benefits from model-based expectations. (Ericsson, Hendry, ; Mizon, 1998).
Models and Test Results
We start by reporting the estimates of the policy reaction function using (10) and (12). The conditional and marginal models are constructed with the demand for money in the US to check if the LC is relevant after the post-crisis monetary policy shift. Quarterly data over 1990 and 2015 are used. The conditional model defines the real money demand as dependent variable. We assume that money demand is identified by a cointegrating vector of both scale variables and the variables representing the opportunity cost of holding money. Judd ; Scadding (1982) and Hurn ; Muscatelli (1992) model similar relations for their studies with different specifications and analysis.
The scale variables in the money demand function represent wealth effects and transactions. Real wealth, which captures the asset motives of holding money, is represented by the proxy of real total financial assets of non-financial corporate sector. The other scale variable is real GDP, representing economic activity and hence, transactions based demand for money.
The second set of variables denotes the opportunity cost of holding money, which consists of both its own rate and alternative returns on money. We did not include own rate of money, since the current deposits’ rates have long been close to zero in the US and do not capture observable changes. As the measure of alternative returns, we added the interest rate on the 3-month US Treasury Bill, regarded as a close money-substitute foregone by holding money. All variables are made real with the GDP deflator. The corresponding marginal models were constructed for real wealth, GDP and interest rates as shown in Table 1.
There are two conditions for superexogeneity as mentioned: for weak exogeneity, the resulting residuals from the marginal model must be insignificant in the conditional model. As per superexogeneity (or structural invariance of the parameters), the parameters of the conditional model must be insensitive to induced structural changes in the marginal model parameters. Policy analysis generally involves changing the marginal process of x_t. For a valid analysis under such changes, the parameters ?_1 should be invariant to those changes/interventions. Ericsson (1992), Hurn & Muscatelli, (1992), Engle & Hendry, (1993), Hendry (1995) and Valadkhani (1998) state the use of a dummy variable to test superexogeneity empirically. This variable is inserted into both conditional and marginal models to represent the structural change or policy shifts. Structural invariance is satisfied, if it comes out significant in the marginal model and simultaneously insignificant in the conditional model. But, the null of superexogeneity will be rejected if the dummy added to the basic conditional model is proven to be significant statistically. The regime shift or structural change dummy variable in this study is defined as ?DUM?_t, which captures the QE policy and takes the value of zero until the fourth quarter of 2008, and one otherwise.
In the first step of estimation, we conducted ADF tests to check for stationarity of the variables and detect their orders of integration. Appendix B displays the test results, which reveal that all variables are integrated of order one, I(1).
We report the estimation results of the parsimonious dynamic conditional model for money demand based on (13) and derived by the general-to-specific (GTS) approach (Davidson, Hendry, Srba, & Yeo, 1978; Engle et al., 1983). Johansen Cointegration Test Results are presented in Appendix C. The short-run dynamics in the model are captured by the cointegrating vector as an error correction mechanism (?ECM?_(t-1)), which is statistically significant. The included dummy variable is of particular interest to us, since it captures structural changes. As expected, the sign of its coefficient estimate is positive, since the QE policy would induce higher demand for money. Its coefficient is also significant in the conditional model, validating doubts on the condition of the structural invariance. This means that shifts in the monetary regime have significant considerable effect on money demand, highlighting the importance of behavioral factors such as expectations, as stated by the LC.
The serial correlation and heteroscedasticity test results are satisfactory. Furthermore, we report the results of cumulative sum (CUSUM) test (Fig.1) documenting that the regression is stable over the sample period.
Equation 13: Conditional Model for US Money Demand
??MD?_t= -0.003?ECM?_(t-1)+ 0.507??MD?_(t-1 )+ 0.24??MD?_(t-3) + 0.044??(W/GDP)?_(t-4) – 0.24??GDP?_(t-1)
0.002 0.076 0.074 0.022 0.101
+ 0.358??GDP?_(t-3) + 0.001??TB?_(t-2)-0.002??TB?_t – 0.045??GDP?_t + 0.001?DUM?_t
0.088 0.0005 0.0005 0.093 0.0005
Sample Period: 1990Q1-2015Q4
R^2=0.594 R ?^2=0.555
Serial Correlation F (4,90) = 1.548
Heteroscedasticity ARCH F (4,95) = 0.9934
Figure 1. CUSUM of the Conditional Model:
The next step in the procedure is to estimate the marginal models for x_t, reported in Table 1. The definitions of the data and additional explanatory variables in the marginal model are detailed and clarified in Appendix A.
Table 1. Marginal Models for x_t
Marginal models qualify to be stable and reveal mainly satisfactory diagnostic results. The marginal model of GDP was estimated using HAC errors to account for heteroscedasticity detected while testing. The signs of all significant coefficient estimates are consistent with established underlying theory, and the ECM displays significant coefficients in all models. Most importantly, included dummies, which capture a major QE shift, also have significant coefficients in all models. This indicates that implementation of the QE plays a crucial role in modelling the main economic relationships in policy modeling, by validating changes in the actual structural parameters of the econometric models. Our empirical findings ascertain that the parameters in the econometric model of the money demand relationship, which is largely used by policymakers, have changed in response to changes in QE regime after 2008. Therefore, the consequent actions of the economic agents, such as their decisions concerning asset accumulation, economic activity and purchase of bonds would largely depend on their expectations, based mainly on the QE policy itself.
Table 2 displays important test results to provide further support to the validity of the LC associated with policy-based expectations. Entire set of residuals from the marginal models are statistically insignificant in the conditional model to document that the condition of weak exogeneity is satisfied. On the other hand, the same is not true for the condition of structural invariance, since the dummy is simultaneously significant in both the marginal model(s) and the conditional model. Based on these findings we conclude that the null of superexogeneity is rejected. We comment that the model we constructed for money demand is prone to the LC.
Table 2. Superexogeneity Test Results
Test Null Hypothesis t-statistic
Weak exogeneity: ?_t^W=0 1.558
Marginal model of W DUM = 0 1.948*
Marginal model of TB DUM = 0 1.718*
Marginal model of GDP DUM = 0 3.356***
Conditional model DUM = 0 1.802*
***, ** and * indicates rejection of the null hypothesis at the 1%, 5% and 10% significance level, respectively.
Discussion and Comments on Policy Implications
Analyzing agents’ expectations and their behavior based on the expectations is essential in setting a credible and efficient central bank policy to manipulate economic activities. As such, our paper addresses an active policy debate while also addressing growing concern about the management of expectations by monetary authorities. We make use of the unconventional monetary policy tool of QE to probe the impact of QE on agents’ behavior. In this regard, anchoring announced to the public appear as a crucial means of shaping the expectations. Yellen (2013) states that well-anchored inflation expectations have proven to be an immense asset in conducting monetary policy after the 2008 crisis. Recent studies stipulate that commitment of the FED to its pre-announced inflation rate and the resulting formation of expectations helped avoid the prolonged disinflationary process associated with the post-crisis high rates of unemployment (Ball & Mazumder, 2015). While adaptive/past-based expectations may be a reasonable premise in some circumstances, predictive monetary policy, transparent communication, and stable expectations play a crucial role, since they influence all sorts of behavior and may help avoid major instabilities predicted by standard modelling. Similarly, Trichet (2010) explains the use of anchoring as “First, the precise quantitative nature of our definition of the price stability objective has proved crucial in anchoring longer-term inflation expectations. And, as a result, it has protected us against both upside and downside risks to price stability, even in these most turbulent of times. The anchoring of private inflation expectations induces a self-correcting mechanism in response to temporary disturbances in price developments, thereby easing the burden on monetary policy.”
Regarding the performance of economic agents in forming the expectations, the global financial crisis set the stage for realization of such expectations’ success or failure, especially for the near future. We exemplify the expectations by two professionals and an institution with primary business of dealing with risk to assess the capability of even the most experienced professionals. In 2005, the FED former chairman, Alan Greenspan stated “Overall, while local economies may experience significant speculative price imbalances, a national severe price distortion (i.e. a housing bubble) seems most unlikely in the United States, given its size and diversity.” The second professional is also a FED chairman, and a professor of macroeconomics with textbooks and influential papers published; Ben S Bernanke stipulated “The risk that the economy has entered a substantial downturn appears to have diminished over the last month or so” in June 2008, only about three months before Lehman Brothers declared bankruptcy on September 15, 2008. The failure in the forecast of two of the most experienced professionals in the US validated the importance of the unpredictable behavior of expectations, which necessitated further investigation. What Greenspan could not anticipate was the lowest price growth correlation jumping from -0.6 to 0.17, a historical unprecedented change. Bernanke’s failure is reasoned by a much larger set of data that was somehow misinterpreted. In addition, the American International Group (AIG), the giant conglomerate specializing in insurance and risk taking, was not able to foresee the upcoming sudden fall of home prices before being filed for bankruptcy.
The ongoing pace of economic variables in their pleasing expected ranges should not make policy designers lose their alertness. As Mishkin (2011b) indicated “Up until August 2007, advances in both theory and empirical work in the study of monetary economics had led both academic economists and policymakers to argue that there was now a well-defined “science of monetary policy”. There was a general consensus in central banks about most elements of monetary policy strategy, and monetary policy was perceived as being highly successful in OECD countries, with not only low inflation, but also low variability of inflation. In addition, output volatility had declined in these countries, and the period since the early 1980s was dubbed the “Great Moderation”. Monetary economists and central bankers were feeling pretty good about themselves.” These were the descriptions of how monetary authorities felt right before the turmoil. Emergence of the macro prudential policy has to be emphasized towards efforts of detecting and preventing crises even before they become effective. Mishkin (2011a) recommends the use of macro prudential policy as “Macro-prudential regulations can be used to dampen the interaction between asset price bubbles and credit provision. Other macro-prudential policies to constrain credit bubbles include dynamic provisioning by banks; lower ceilings on loan-to-value ratios or higher haircut requirements for repo lending during credit expansions; and Pigouvian-type taxes on certain liabilities of financial institutions.”
Economists agree on the fact that the shocks to the financial system resulting from the global financial crisis were in many ways more complicated compared to those triggered by the Great Depression of the 1930s, and yet, the consequent contraction of economic activity appeared to be less severe (Mishkin, 2011b). Although Taylor (2014) believes that post-crisis aggressive monetary policy was not as effective as expected, Mishkin (2011b) suggests it was the best tool that could be implemented to mitigate the shocks, since the severity of the crisis in 2008 overwhelmed the ability of conventional monetary policy to counteract it. Except for efficiency debates, the regime changes rekindled questions on the Lucas Critique that naturally arise in the environment of major policy shift.
Following the emergence of the LC, monetary models posed challenges in regard to their potency to explain/forecast inflation dynamics and as a policy tool, due to their inability to accurately capture the behavior of the agents after a shift. According to the main argument of Lucas, any change in the macroeconomic policy, such as QE in our case, will alter the expectations of the agents who make assessments by considering the future rather than the past and they will adapt their expectations and behavior to the new policy stance. Lucas stressed on the parameters of the econometric model that become unstable across different policy regimes. Monetary shifts such as the QE policy carry high possibility to alter the structure of past-data-based economic models, as foreshadowed in the LC. If the LC holds, it is deceptive to focus solely on the past when economic consequences of such policies are determined, whereby expectations play a significant role in shaping them. Indeed, the management of expectations about future policy has become a central element of monetary theory with zero-bound policies, as highlighted in Mishkin (2011b).
At the same time, the QE period represents an interesting and unique case of study. Our empirical estimates reject the condition of superexogeneity or parameter invariance, providing credibility to the LC. This is contrary to Hurn & Muscatelli (1992) which seems to be the only empirical paper that tests LC validity via superexogeneity methodology (in the example of the UK money demand over the period 1966Q4-1989Q4). Several other works (Bajo-Rubio et al., 2007; Estrella & Fuhrer, 2003; Leeper & Zha, 2003) generally found no or modest quantitative impact of LC in monetary relationships, while Rudebusch (2005) argues that the main reason why most of the studies fail to detect the LC is that shifts in the policy rule may be unimportant historically. Indeed, the QE period represents the opportunity of radical policy shifts capturing massive liquidity provisions, purchases of both government and private assets, and dramatic expansion of the FED’s balance sheet. This might be one explanation for our results that significantly support the validity of the LC in the model of money demand in the US.
In the context of our findings, what policymakers should consider is how to deal with those parameter inconstancies and therefore, with expectations. The instability of monetary models in the presence of structural breaks (following regime shifts) would mean considerable challenge for their use as a policy tool. However, Bernanke (2009) suggests that expectations, if effectively monitored, can rather be used as an additional tool to manage the implications of policy changes, especially in the environment of zero-bound policy. As the former FED chairman Yellen (2013) stressed, management of expectations has proven to be an immense asset in conducting post-crisis policies and minimizing policies’ potential costs to the economy.
The theoretical literature strongly supports expectation management to stimulate consumption during the zero-bound period because a commitment to maintain low short-term interest rates for a longer time triggers lower long-term interest rates and simultaneously raises inflation expectations, thereby reducing the real interest rates, and helping to continue zero-bound policies for a long period of time (Eggertsson & Woodford, 2003). With strong commitment, clear communication and broad guarantees, policymakers can actually get the agents to react more for new policies. Many of the actual programs implemented during the crisis had elements of guarantees, although they could use them more extensively (Caballero, 2010). The IMF (2013) stipulates that providing maximum clarity to the public about the expansionary policies (thereby anchoring long-term inflation expectations) helped the FED avoid prolonged deflation that started after the crisis, and at the same time, increase its flexibility to use securities purchases to provide additional accommodation. For instance, the rate of US core inflation in 2011 was close to its level before 2008, despite the short-run prediction of the Phillips curve that high unemployment rates would drag inflation rates well below zero (Ball & Mazumder, 2015). The paper suggests that one of the reasons for this is that the Fed’s commitment to a 2% inflation target has kept expected inflation near 2%, which in turn has prevented actual inflation from falling very far below that level.
The use of a monetary policy based on QE1-2-3, overall, was an accomplishment and helpful to mitigate destructive shocks by the financial system. The FED was largely successful in administering and even manipulating the expectations – as suggested by Lucas – and made use of drastic change in the monetary policy regime to keep the growth rate, as well as the unemployment rate, at desirable levels despite the disastrous magnitude of the global financial crisis. The trends in the US growth, unemployment and inflation rates provided in Figure 2, in fact, support relative success of those combined policies.
Currently, central banks use models free from the LC. As indicated by Israel (2016), the Fed employs two DSGE models, which are revised and extended versions of the models presented in Christiano, Eichenbaum, ; Evans (2005) and Smets ; Wouters (2007), respectively. Similarly, two of the most important models used by the ECB are the New Area White Model, based on Smets ; Wouters (2003), and the CMR Model based on Christiano, Motto, ; Rostagno (2010).
Figure 2. Actual and graphical output of US GDP Growth, Inflation, and Unemployment Rates, (2000-2016)
(annual %) Unemployment (% of total labour force) Inflation,
2000 4,09 4,00 2,28
2001 0,98 4,70 2,28
2002 1,79 5,80 1,54
2003 2,81 6,00 1,99
2004 3,79 5,50 2,75
2005 3,35 5,10 3,22
2006 2,67 4,60 3,07
2007 1,78 4,60 2,66
2008 -0,29 5,80 1,96
2009 -2,78 9,30 0,76
2010 2,53 9,60 1,22
2011 1,60 8,90 2,06
2012 2,22 8,10 1,84
2013 1,68 7,40 1,62
2014 2,37 6,20 1,79
2015 2,60 5,30 1,08
2016 1,62 4,91 1,32
Another example of preparing and managing expectations can be observed in the gradual increase of interest rates with the first actual tightening in December 2015. The increase in the rates was sufficiently small and gradual, accompanied by prior effective communications with the public, having provided clear signals about future tightening. As a consequence, both domestic and international impacts were smooth, while relative depreciation of other currencies against the dollar had started well before the actual FED’s tightening. This is largely due to the expectations formed by the speeches of the FED chairpersons from 2013 about their intentions to gradually temper the QE regime.
As Bernanke (2009) mentioned, the FED prompted considerable effort in “developing a suite of tools to ensure that the exit from highly accommodative policies can be smoothly accomplished when appropriate, and FOMC participants have spoken publicly about these tools on numerous occasions”. Given the existence of structural breaks and associated expectation changes documented by our results, a central bank commitment that firmly anchors long-run inflation expectations can make an important contribution to the effectiveness of its policies aimed at stabilizing and stimulating economic activity in the face of adverse demand shocks. The recommended acts would include continuing to actively review its communication strategy, and to make its outlook and policy intentions as clear as possible. The commitment to certain nominal anchors is not necessarily limited to inflation expectations, but also extends to other indicators such as money supply and exchange rate. Our evidence of the superexogeneity in this work compatibly highlights the crucial role of the management of expectations, seemingly shaped by the policy itself. Transparency, communication and credible commitment of the central banks have become important elements for successful monetary policy outcomes, which are truly possible under the condition of central bank independence.
Alzaabi, D. A. M. (2013). Where Does the WTO Stand in the Global Economic Recession. SSRN Electronic Journal. https://doi.org/10.2139/ssrn.2267114
Bajo-Rubio, O., Díaz-Roldán, C., & Esteve, V. (2007). Change of regime and Phillips curve stability: The case of Spain, 1964-2002. Journal of Policy Modeling, 29(3), 453–462. https://doi.org/10.1016/j.jpolmod.2006.06.017
Ball, L., & Mazumder, S. (2015). A Phillips Curve with Anchored Expectations and Short-Term Unemployment. IMF Working Paper, (39). https://doi.org/10.3386/w20715
Banerjee, A., Hendry, D. F., & Mizon, G. E. (1996). The econometric analysis of economic policy. Environment and Development in Ireland, 407–423. Retrieved from http://eprints.soton.ac.uk/32883/
Barro, R. J. (1976). Rational expectations and the role of monetary policy. Journal of Monetary Economics, 2(1), 1–32. Retrieved from ftp://ftp.soc.uoc.gr/students/master/macro/Barro – JME (1976).pdf
Begg, D. K. H. (1982). Rational Expectations, Wage Rigidity and Involuntary Unemployment: A Particular Theory. Oxford Economic Papers, 34, 23–47. https://doi.org/10.2307/2662738
Belke, A. (2000). Partisan political business cycles in the German labour market?? Empirical tests in the light of the Lucas-critique ?, (May 1998), 225–283.
Bernanke, B. S. (2009). Opening Remarks?: The Economic Outlook and Monetary Policy, 1–16.
Bernanke, B. S. (2012). The Fed – Monetary Policy since the Onset of the Crisis. Retrieved April 3, 2017, from https://www.federalreserve.gov/newsevents/speech/bernanke20120831a.htm
Boug, P. (1999). The Demand for Labour and the Lucas Critique. Evidence from Norwegian Manufacturing. Research Department of Statistics, Norway, Discussion Papers 256.
Caballero, R. J. (2010). Macroeconomics after the Crisis: Time to Deal with the Pretense-of-Knowledge Syndrome. Journal of Economic Perspectives, 24(4), 85–102. https://doi.org/10.1257/jep.24.4.85
Cagan, P. (1956). The monetary dynamics of inflation, in studies in the quantity theory of money. ed. M. Friedman. University of Chicago Press.
Caporale, G. M. (1996). Testing for superexogeneity of wage equations. Applied Economics, 28, 663–672.
Chirinko, R. S. (1988). Business Tax Policy, The Lucas Critique, and Lessons from the 1980’s. American Economic Review, 78(2). Retrieved from http://search.ebscohost.com/login.aspx?direct=true;db=bth;AN=4505614;site=ehost-live;scope=site
Chow, G. C. (1960). Tests of equality between sets of coefficients in two linear regressions. Econometrica, 591–605.
Christiano, L. J., Eichenbaum, M., ; Evans, C. L. (2005). Nominal rigidities and the dynamic effects of a shock to monetary policy. Journal of Political Economy, 113(1), 1–45. Retrieved from https://www.journals.uchicago.edu/doi/abs/10.1086/426038
Christiano, L., Motto, R., ; Rostagno, M. (2010). Financial factors in economic fluctuations. Retrieved from https://papers.ssrn.com/sol3/papers.cfm?abstract_id=1600166
Davidson, J. E., Hendry, D., Srba, F., ; Yeo, S. (1978). Econometric Modelling of the Aggregate Time-Series Relationship Between Consumers’ Expenditure and Income in the United Kingtom. The Economic Journal, 88, 661–692.
Eggertsson, G. B., & Woodford, M. (2003). The Zero Bound on Interest Rates and Optimal Monetary Policy. Brookings Papers on Economic Activity, 34(1), 139–235. https://doi.org/10.1353/eca.2003.0010
El-Shagi, M., & Giesen, S. (2013). Money and inflation: Consequences of the recent monetary policy. Journal of Policy Modeling, 4(35), 520–537.
Engle, R. F., & Hendry, D. F. (1993). Testing superexogeneity and invariance in regression models. Journal of Econometrics, 56(1–2), 119–139. https://doi.org/10.1016/0304-4076(93)90103-C
Engle, R. F., Hendry, D. F., & Richard, J.-F. (1983). Exogeneity. Journal of Econometric Society, 277–304.
Ericsson, N. R. (1992). Cointegration, exogeneity, and policy analysis: An overview. Journal of Policy Modeling. https://doi.org/10.1016/0161-8938(92)90001-S
Ericsson, N. R., Hendry, F. D., & Mizon, G. E. (1998). Exogeneity, Cointegration, and Economic Policy Analysis. International Finance Discussion Papers, Number 616(June).
Ericsson, N. R., & Irons, J. S. (1995). The Lucas critique in practice: theory without measurement. International Finance Discussion Papers.
Estrella, A., & Fuhrer, J. C. (2003). Monetary policy shifts and the stability of monetary policy models. The Review of Economics and Statistics, 85(1), 94–104.
Fahr, S., Motto, R., Rostagno, M., Smets, F., & Tristani, O. (2011). Lessons for monetary policy strategies from the recent past (In Approaches to monetary policy revisited–Lessons from the crisis ). Retrieved from https://lirias.kuleuven.be/handle/123456789/338490
Fair, R. C. (1987). Macroeconmetric models. The New Palgrave: A Dictionary of Economics, 3, 269–273.
Faria, J. R., & León-Ledesma, M. A. (2005). Real exchange rate and employment performance in an open economy. Research in Economics, 59(1), 67–80. https://doi.org/10.1016/j.rie.2004.12.005
Favero, C., & Hendry, F. D. (1992). Testing the Lucas critique: A review. Econometric Reviews, 11(3), 265–306. https://doi.org/10.1080/07474939208800238
Fischer, S. (1980). On Activist Monetary Policy with Rational Expectations. University of Chicago Press, 211–247. Retrieved from http://www.nber.org/chapters/c6265.pdf
Friedman, M. (1956). Studies in the quantity theory of money. University of Chicago Press, 561.
Friedman, M. (1968). The role of monetary policy. American Economic Review, 58, 1–17.
Giersbergen, N., & Kiviet, J. F. (1996). No Title. Oxford Bulletin of Economics and Statistics, 58(4), 631–656.
Gordon, R. J. (1976). Can econometric policy evaluations be salvaged. Brunner, and Meltzer Op. Cit.
Habibullah, M. S., Azali, M., & Baharumshah, A. Z. (2001). Money, income and the Lucas critique: the case for Malaysia. Analisis, 8(1&2), 69–85. Retrieved from http://repo.uum.edu.my/431/
Hendry, D. F. (1988). The Encompassing Implications of Feedback versus Feedforward Mechanisms in Econometrics. Oxford Economic Papers, 40, 132–149. https://doi.org/10.2307/2663257
Hendry, D. F. (1995). Dynamic Econometrics. Oxford University Press on Demand.
Hendry, D. F. (2002). Forecast failure, expectations formation and the lucas critique. Annales d’Économie et de Statistique, 21–40. Retrieved from https://www.jstor.org/stable/pdf/20076341.pdf
Hurn, A. S., ; Muscatelli, V. A. (1992). Testing Superexogeneity: the Demand for Broad Money in the Uk. Oxford Bulletin of Economics and Statistics, 54(4), 543–556. https://doi.org/10.1111/j.1468-0084.1992.mp54004004.x
Israel, K.-F. (2016). Modern Monetary Policy Evaluation and the Lucas Critique. Dialogi Polityczne, 19, 123–145. Retrieved from http://apcz.umk.pl/czasopisma/index.php/DP/article/view/DP.2015.022
Judd, J. P., ; Scadding, J. L. (1982). The Search for a Stable Money Demand Function: A Survey of the Post-1973 Literature. Jounal of Economic Literature, 20(3), 993–1023. Retrieved from http://www.jstor.org/stable/2724409?seq=1#page_scan_tab_contents
Karagiannis, S., Panagopoulos, Y., ; Vlamis, P. (2010). Interest rate pass-through in Europe and the US: Monetary policy after the financial crisis. Journal of Policy Modeling, 32(3), 323–338. https://doi.org/10.1016/j.jpolmod.2010.02.006
Karunaratne, N. D. (1996). Growth and trade dynamics under regime shifts in Australia. Journal of Economic Studies, 23(2), 55–69.
Kydland, F. E., ; Prescott, E. C. (1977). Rules Rather than Discretion: The Inconsistency of Optimal Plans. Journal of Political Economy, 85(3), 473–491. https://doi.org/10.1086/260580
Leeper, E. M., ; Zha, T. (2003). Modest policy interventions. Journal of Monetary
Economics, 50(8), 1673–1700. https://doi.org/10.1016/j.jmoneco.2003.01.002
Lindé, J. (2001). Testing for the Lucas critique: A quantitative investigation. American Economic Review, 91(4), 986–1005.
Liu, Y., ; Morley, J. (2014). Structural evolution of the postwar U.S. economy. Journal of Economic Dynamics and Control, 42, 50–68. https://doi.org/10.1016/j.jedc.2014.03.002
Lubik, T. A., ; Surico, P. (2010). The lucas critique and the stability of empirical models. Journal of Applied Econometrics, 25(1), 177–194. https://doi.org/10.1002/jae.1129
Lucas, R. E. (1976). Econometric policy evaluation: A Critique. Carnegie-Rochester Conference Series on Public Policy, 1(1), 19–46. https://doi.org/10.1080/000368497327344
Lucas, R. E., ; Prescott, E. C. (1971). Investment Under Uncertainty. Econometrica, 39(5), 659. https://doi.org/10.2307/1909571
Lucas, R. E., ; Sargent, T. (1981). Rational expectations and econometric practice. University of Minnesota Press.
Malinvaud, E. (1997). L’économétrie dans l’élaboration théorique et l’étude des politiques. L’Actualité Économique, 73(1-2–3), 11–25.
Mishkin, F. S. (1995). The rational expectations revolution: a review article of: Preston J. Miller, ed.: The rational expectations revolution, readings from the front line. National Bureau of Economic Research., No. w5043. Retrieved from http://www.nber.org/papers/w5043
Mishkin, F. S. (2009). Is monetary policy effective during financial crises? American Economic Review , 99(2), 573–77. Retrieved from https://core.ac.uk/download/pdf/6586531.pdf
Mishkin, F. S. (2011a). How Should Central Banks Respond to Asset-Price Bubbles? The “Lean” versus “Clean” Debate After the GFC. Retrieved from http://www.gsb.columbia.edu/faculty/fmishkin/
Mishkin, F. S. (2011b). Monetary Policy Strategy: lessons from the crisis. National Bureau of Economic Research.
Muth, J. F. (1961). Rational Expectations and the Theory of Price Movements. Econometrica, 29(3), 315–335. Retrieved from http://www.parisschoolofeconomics.eu/docs/guesnerie-roger/muth61.pdf
Oliveira, M. A., ; Santos, C. (2007). Modelling the German Yield Curve and Testing the Lucas. Applied Econometrics and International Development, 7(1).
Psaradakis, Z., ; Sola, M. (1996). On the power of tests for superexogeneity structural invariance. Journal of Econometrics, 72, 151–175.
Recession in Perspective | Federal Reserve Bank of Minneapolis. (n.d.). Retrieved April 3, 2017, from https://www.minneapolisfed.org/publications/special-studies/rip/recession-in-perspective
Rogoff, K. (2017). Monetary Policy in a Low Interest Rate World. Journal of Policy Modeling.
Rudebusch, G. (2005). Assessing the Lucas critique in monetary policy models. Journal of Money, Credit and Banking, 37(2), 245–72. https://doi.org/10.1353/mcb.2005.0024
Salmon, M., ; Marcellino, M. (2001). Robust Decision Theory and the Lucas Critique. Warwick Business School, Finance Group. Retrieved from https://econpapers.repec.org/RePEc:wbs:wpaper:wp01-10
Santos, C. (2004). Extending the Superexogeneity Tests To Account for Unknow Break Dates. Retrieved from http://220.127.116.11/conferences/cfl/files/CFLPapersFinal/CarlosSantos.pdf
Sargent, T. J. (1977). The Demand for Money during Hyperinflations under Rational Expectations: I. International Economic Review, 18(1), 59. https://doi.org/10.2307/2525769
Sargent, T. J., Fand, D., ; Goldfeld, S. (1973). Rational Expectations, the Real Rate of Interest, and the Natural Rate of Unemployment. Brookings Papers on Economic Activity, 1973(2), 429. https://doi.org/10.2307/2534097
Sargent, T. J., ; Wallece, N. (1975). ” Rational ” Expectations , the Optimal Monetary Instrument , and the Optimal Money Supply Rule. University of Chicago Press, 83(2), 241–254.
Sheffrin, S. M. (1996). Rational Expectations. Cambridge University Press. Retrieved from https://books.google.com.tr/books?hl=tr;lr=;id=nkLzXjsMgbEC;oi=fnd;pg=PR9;dq=sheffrin+%221983%22+rational+expectations;ots=tgNKbim0ab;sig=kOhqYQ8meu_eYQypGGc1VzFQol0;redir_esc=y#v=onepage;q=sheffrin %221983%22 rational expectations;f=false
Shiller, R. J. (1978). Rational expectations and the dynamic structure of macroeconomic models: A critical review. Journal of Monetary Economics, 4(1), 1–44. https://doi.org/10.1016/0304-3932(78)90032-6
Sims, C. A. (1986). Are forecasting models usable for policy analysis? Federal Reserve Bank of Minneapolis Quarterly Review, 10(1), 2–16.
Sims, C. A. (2007). Monetary Policy Models. Brooking Papers on Economic Activity, (2), 75–87. https://doi.org/10.1353/eca.2008.0005
Sims, C. A., Goldfeld, S. M., ; Sachs, J. D. (1982). Policy analysis with econometric models. Brookings Papers on Economic Activity, 1, 107–164.
Smets, F., ; Wouters, R. (2003). An Estimated Dynamic Stochastic General Equilibrium Model of the Euro Area. Journal of the European Economic Association, 1(5), 1123–1175. https://doi.org/10.1162/154247603770383415
Smets, F., ; Wouters, R. (2007). Shocks and Frictions in US Business Cycles: a Bayesian DSGE Approach. American Economic Review, 97(3), 586–606. Retrieved from http://hdl.handle.net/10419/144322www.econstor.eu
Smith, R. (2009). EMU and the Lucas Critique. Economic Modelling, 26(4), 744–750. https://doi.org/10.1016/j.econmod.2008.07.008
Taylor, J. B. (2014). Rapid Growth or Stagnation: An Economic Policy Choice. Journal of Policy Modeling, 36(4), 641–648.
Trichet, J.-C. (2010). Reflections on the nature of monetary policy non-standard measures and finance theory. In ECB Central Banking Conference. Frankfurt. Retrieved from https://www.ecb.europa.eu/press/key/date/2010/html/sp101118.en.html
Valadkhani, A. (1998). Effect of government capital expenditure on GDP in the Iranian economy using superexogeneity testing. Applied Economics Letters, 5(6), 361–364. https://doi.org/10.1080/135048598354726
Verick, S.?;, ; Iyanatul Islam. (2010). The Great Recession of 2008-2009: Causes, Consequences and Policy Responses. Retrieved from http://hdl.handle.net/10419/36905
Yellen, J. (2013). Panel Discussion on ‘Monetary Policy: Many Targets, Many Instruments. Where Do We Stand?
Appendix A: Description of the Data and Variables
?MD?_t Log (Real Money Demand M2)
?GDP?_t Log (Real Gross Domestic Product)
?TB?_t 3-Month Treasury Bill Rate
?W/GDP?_t Real Wealth of Firms (as % of GDP)
W_t Log (Real Wealth)
?SMI?_t Log (S&P Stock Market Index)
?INF?_t Log (GDP deflator)
L_t Log (Labor Participation Ratio)
C_t Log (Real Capital)
?DUM?_t Dummy Variable that takes 0 between
1990Q1-2008Q3 and 0 otherwise
Appendix B: Augmented Dickey-Fuller (ADF) Test Results
None 3.667 0.999
Intercept 2.194 0.999
Trend and intercept -2.373 0.391
Wealth / GDP
None 1.739 0.979
Intercept -0.859 0.797
Trend and intercept -1.820 0.688
None 4.678 1.000
Intercept -1.591 0.483
Trend and intercept -0.776 0.964
Treasury Bill Rate None -1.817 0.066
Intercept -2.036 0.270
Trend and intercept -4.597 0.001
Inflation None 4.239 1.000
Intercept -2.612 0.093
Trend and intercept -2.416 0.368
Wealth None 2.572 0.997
Intercept -1.159 0.689
Trend and intercept -1.459 0.837
Stock Market Index None 2.377 0.995
Intercept -1.588 0.484
Trend and intercept -1.846 0.675
Capital None 2.913 0.999
Intercept -1.748 0.404
Trend and intercept -1.111 0.921
Labour None -1.813 0.066
Intercept 1.695 0.999
Trend and intercept -0.87 0.954
Appendix C: Johansen Cointegration Test
Conditional Model for Money Demand
Eigenvalue Trace Statistic 0.05 Critical Value Prob.**
None* 0.254 59.877 47.856 0.002
At most 1 0.133 28.455 29.797 0.070
Marginal Model for Wealth
Eigenvalue Trace Statistic 0.05 Critical Value Prob.**
None* 0.193 38.421 29.797 0.004
At most 1 0.094 14.979 15.494 0.059
(c) Marginal Model for Treasury Bill Rate
Eigenvalue Trace Statistic 0.05 Critical Value Prob.**
None* 0.127 27.693 29.797 0.085
At most 1 0.08 13.129 15.494 0.110
Marginal Model for GDP
Eigenvalue Trace Statistic 0.05 Critical Value Prob.**
None* 0.261 37.467 29.797 0.005
At most 1 0.039 4.395 15.494 0.869